Affiliations
Division of Hospital Medicine, Washington University School of Medicine, St. Louis, Missouri
Given name(s)
Kevin
Family name
Heard
Degrees
BS

Prevention of Inpatient Hypoglycemia

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Prevention of inpatient hypoglycemia with a real‐time informatics alert

Insulin therapy in the hospital setting can cause hypoglycemia, which may lead to increased mortality and length of stay (LOS).[1, 2, 3] Hypoglycemia is associated with cardiovascular, cerebrovascular, and patient fall events.[4, 5] The Centers for Medicare and Medicaid Services have designated both severe hypoglycemia (SH) with harm and diabetic ketoacidosis as hospital acquired conditions (HAC) or never events. The Society for Hospital Medicine (SHM) defines SH in the hospital as a blood glucose (BG) <40 mg/dL. Minimizing episodes of SH is important for patient health outcomes, patient safety, and for healthcare facilities' safety metrics.

Many factors contribute to SH including excessive insulin doses, medication errors, inappropriate timing of insulin doses with food intake, changes in nutritional status, impaired renal function, and changes in medications such as steroids.[6] As part of a multiyear project in patient safety, an inpatient hypoglycemia alert algorithm was developed based on a multivariate analysis of individual patient demographic, pharmacy, laboratory, and glucometric data. The algorithm was previously shown to have a 75% sensitivity to predict episodes of SH.[7] In this study, we tested whether a predictive real‐time informatics hypoglycemia alert based on the tested algorithm, along with trained nurses, would result in a decreased frequency of SH events compared to usual care. We hypothesized that this alert would result in a reduction of SH events in those patients at high risk for hypoglycemia.

METHODS

Study Design and Population

This prospective cohort‐intervention study involved inpatients admitted to Barnes‐Jewish Hospital in St. Louis, Missouri, the academic hospital of Washington University School of Medicine (WUSM), from August 2011 through December 2011. Fourteen floors, including 10 internal medicine and 4 cardiology medicine floors, were selected based upon a high frequency of severe hypoglycemic events noted in 2010. Six of the internal medicine floors were designated as intervention floors, and 8 were designated as control floors, including the 4 cardiology units. The study population consisted of patients receiving diabetic medications on study floors who had a BG <90 mg/dL during their hospital stay (Figure 1). The study was approved by the WUSM institutional review board and included a waiver of consent for individual patients.

Figure 1
Study enrollment.

The pharmacy informatics system was programmed with the previously developed hypoglycemia alert to prospectively identify those patients at high risk of hypoglycemia based on real‐time patient information.[7] Patients were identified as high risk on study floors if insulin or an oral antihyperglycemic agent was prescribed and if their hypoglycemia informatics generated risk score was >35 within 24 hours of having a capillary or venous BG<90 mg/dL. The risk score of 35 corresponded to a 50% sensitivity for a subsequent BG <60 mg/dL and a 75% sensitivity for a BG <40 mg/dL. Patients who generated an alert once during their hospital stay were assigned to 1 of 3 categories based on their admission division and risk score: high‐risk intervention (HR‐I), high‐risk control (HR‐C), or low risk (LR). LR patients also had a BG <90 mg/dL during their stay, but a risk score of <35.

The electronic alert for HR‐I patients was sent by pager to division‐specific charge nurses. Fourteen charge nurses on intervention divisions were trained to assess the alert, interview the patient, identify an alternate dosing strategy, and collaborate with the patient's physicians. HR‐C patients were identified on control divisions based on the same criteria as intervention patients, but no alert was generated. Control patients' charts were reviewed and evaluated upon discharge by the research team‐certified diabetes nurse educator to determine whether the treating physician had identified the SH risk and had changed insulin orders.

Nurses and physicians caring for patients on study divisions provided informed consent to participate in the study. Nurses' satisfaction with the alert process and physician interaction was assessed with a collaboration scale that was completed after each alert (see Supporting Information, Appendix A, in the online version of this article).[8]

Alert Development Process

The alert equation algorithm was developed at Barnes‐Jewish Hospital after a retrospective analysis of hospital glucometric data, including capillary and venous BG measurements, and demographic and pharmacy data over a 6‐month time period.[9] The analysis identified factors that were independently associated with hypoglycemia and used these variables in a mathematical model to achieve a 50% sensitivity to predict a subsequent BG of <60 mg/dL and a 75% sensitivity to predict SH.[7] Table 1 outlines the variables in the model and provides the risk‐score equation used to generate an alert.

Variables Identified as Conferring Higher Risk for Hypoglycemia in the Alert and Risk Equation
VariableDescription of Variable
Body weightPatients at a lower weight were at an increased risk. The variable had a linear response, and 3 levels were used to modify the risk equation: <69 kg, 7079 kg, and >80 kg.
Creatinine clearancePatients with a lower creatinine clearance were at an increased risk. This variable had a linear response, and 2 levels were used to modify the risk equation: <48 mL/min or >48 mL/min.
Basal insulin doseIncreased risk was noted at a doses of basal insulin >0.25 U/kg.
Basal‐only dosingDosing of basal insulin without meal‐time insulin conferred increased risk.
Nonstandard insulin therapyThe use of 70/30 insulin was associated with increased risk.
Oral diabetic therapyUse of sulfonylureas was associated with increased risk.
Risk score equation(Value <60)=0.055+1.062 * (Basal <0.25 U/kg)+1.234 * (Basal 0.25 U/kg) & minus;0.294 * (Weight <6069 kg)0.540 * (Weight 7079 kg)0.786 * (Weight 80 kg) & minus;0.389 * (Creatinine Clearance <3847) 0.680 * (Creatinine Clearance 48) 0.239 * (Sliding Yes) 0.556*(Meal Yes)+0.951 * (Sliding and Meal)+0.336 * (Sulfonylurea Yes) Score=100 * (Exp (Value <60)/(1+Exp (Value <60))

The alert used a BG cutoff of 90 mg/dL in accordance with the American College of Endocrinology Hospital Guideline. Although current guidelines from the SHM recommend keeping BG values >100 mg/dL for patient safety, our analysis found that the cutoff of 90 mg/dL had better sensitivity and specificity than the <100 mg/dL guideline for the risk algorithm.[10, 11]

Nurse and Physician Training

Charge nurses received 5 hours of hyperglycemia management training in 3 sessions utilizing a structured curriculum. Session 1 included a pretest followed by diabetes management education. Session 2 was devoted to an interactive workshop utilizing case‐based scenarios of diabetes management problems and hypoglycemia prevention. The final session provided instructions on the electronic alert communication process. Nurses were empowered with tools for effective communication practices using the situation‐background‐assessment‐recommendation (SBAR) technique.[12]

Physicians, including hospitalists and medicine residents on intervention and control floors, took a pretest, received a 1‐hour lecture, and completed the same curriculum of case‐based scenarios in an online self‐directed learning module. Physicians did not receive SBAR training. Both nurses and physicians received pocket cards with insulin management guidelines developed by our research team to ensure that all clinicians had common prescribing practices.[13]

Outcomes

The primary outcome was the incidence of SH occurring in HR‐I versus HR‐C patients. Secondary outcomes included: episodes of SH in LR study patients, incidence of BG<60 mg/dL frequency of transfer to a higher level of care, incidence of severe hyperglycemia defined as BG >299 mg/dL, frequency that high‐risk patient's orders were changed to reduce hypoglycemia risk in response to the alert‐intervention process, LOS, mortality, and a nurse‐physician collaboration scale score.[14]

Statistical Analysis

Demographic and clinical metrics were compared between HR‐I and HR‐C patients to evaluate potential sources of bias. These included age, weight, serum creatinine, creatinine clearance (measured by Cockcroft‐Gault), hemoglobin A1c (HbA1c) if available, LOS, gender, admitting diagnosis, type of diabetes, and Charlson Comorbidity Index score. The alert risk‐score was also compared between intervention and control floors. Two‐tailed t tests assessed differences between the study groups on normally distributed variables, whereas Wilcoxon rank sum tests were used for non‐normally distributed variables, and 2 tests were used for categorical variables. Two‐tailed Fisher exact tests compared the prevalence of hypoglycemia thresholds between the study groups. 2 analysis was used to compare the proportion of patients who experienced a BG >299 mg/dL between intervention and controls and the proportion of orders changed in HR‐I versus HR‐C patients. Logistic regression was used to test the association of nurse collaboration score with the likelihood of orders being changed.

Based on previous research, we estimated a 48% rate of hypoglycemia <60 mg/dL in HR‐C patients on control floors.[7] We calculated a sample size of 195 subjects in each high‐risk group as the number needed for the intervention to produce a clinically meaningful reduction in hypoglycemia of 25% on the intervention floor compared to the control floors with 90% power.

RESULTS

Study Cohort and Patient Characteristics

One hundred ninety‐five patients who met criteria for high‐risk status were enrolled on HR‐I floors and HR‐C floors for a total of 390 high‐risk patients. During the same time period, 265 LR patients were identified on intervention (153 patients) and control (112 patients) floors. The HR‐I patients were similar to the HR‐C patients by baseline demographics, as shown in Table 2. HbA1c was not available on all patients, but the mean HbA1c in the HR‐I group was 7.93% versus 7.40% in the HR‐C group (P=0.048). The Charlson Comorbidity Index score was significantly different between the high‐risk groups (HR‐I: 6.48 vs HR‐C: 7.48, P=0.002), indicating that the HR‐C patients had more comorbidities.[15] There were significant differences in 2 of the 3 most common admitting diagnoses between groups, with more HR‐C patients admitted for circulatory system diseases (HR‐C: 22.3% vs HR‐I: 4.4%, P=0.001), and more HR‐I patients admitted for digestive system diseases (HR‐I: 13.7% vs HR‐C: 3.3%, P<0.001). The proportion of patients with preexisting type 2 diabetes did not differ by intervention status (HR‐I: 89.8% vs HR‐C: 92.0%, P=0.462).

Baseline Patient Characteristics
DemographicHR‐I, Mean SD/Frequency (%), N=195HR‐C, Mean, SD/Frequency (%), N=195Low Risk, Mean, SD/Frequency (%), N=265P Value*
  • NOTE: Abbreviations: HR‐C, high‐risk control; HR‐I, high‐risk intervention. *HR‐I vs HR‐C.

Age, y60.2 (15.1)60.3 (16.9)61.0 (13.8)0.940
Weight, kg84.9 (31.9)80.8 (26.6)93.6 (28.7)0.173
Serum creatinine, mg/dL2.06 (2.56)2.03 (1.87)1.89 (2.17)0.910
Creatinine clearance, mL/min50.6 (29.8)45.4 (27.1)55.5 (29.3)0.077
Hemoglobin A1c, n (%) with data7.93 (2.46), n=130 (67%)7.40 (1.75), n=115 (59%)6.65 (2.05), n=152 (57%)0.048
Risk score52 (11)54 (11)26 (6)0.111
Length of stay, median, d5.835.885.790.664
Male gender84 (43.1%)98 (50.3%)145 (54.7%)0.155
Type 2 diabetes167 (89.8%)172 (92.0%)219 (95.6%)0.462
Charlson Comorbidity Index score6.48 (3.06)7.48 (3.28)6.66 (3.24)0.002
Admit diagnosis endocrine, nutritional, metabolic diseases, and immunity disorders (codes 240279)17 (9.3%)10 (5.4%)11 (4.3%)0.153
Admit diagnosis disease of circulatory system (codes 390459)8 (4.4%)41 (22.3%)26 (10.1%)<0.001
Admit diagnosis disease of digestive system (codes 520579)25 (13.7%)6 (3.3%)27 (10.5%)<0.001
Admit diagnosis diseases of the genitourinary system (codes 580629)6 (3.3%)4 (2.2%)15 (5.8%)0.510
Admit diagnosis reported only as signs, symptoms, or ill‐defined conditions (codes 780799)77 (42.3%)92 (50.0%)121 (46.9%)0.140

Study Outcomes

The rate of hypoglycemia was compared between 195 HR‐I and 195 HR‐C patients, and it should be noted that each patient could generate only 1 episode of hypoglycemia during an admission. As shown in Table 3, the incidence of a BG <60 mg/dL was significantly lower in the HR‐I patients versus the HR‐C patients (13.3% vs 26.7%, P=0.002) as was the incidence of a BG <40 mg/dL (3.1% HR‐I vs 9.7% HR‐C, P=0.012). This represents a decrease of 50% in moderate hypoglycemia (BG <60 mg/dL) and a decrease of 68% in SH (BG <40 mg/dL) between HR‐I and HR‐C patients. Severe hyperglycemia occurrences were not significantly different between intervention and control floors at 28% each.

Rate of Hypoglycemia in Alerted Patients
Alerted Patients Glucose ThresholdHR‐I (%), N=195HR‐C (%), N=195Low Risk (%), N=265P Value*
  • NOTE: Abbreviations: BG, blood glucose; HR‐C, high‐risk control; HR‐I, high‐risk intervention. *HR‐I vs HR‐C.

With BG <40 mg/dL6 (3.1%)19 (9.7%)10 (3.8%)0.012
With BG <60 mg/dL26 (13.3%)51 (26.7%)50 (18.9%)0.002
With BG >299 mg/dL53 (28.0%)53 (27.9%)29 (11.9%)0.974

The sensitivity, specificity, and predictive values of the alert for BG thresholds of <40 mg/dL and <60 mg/dL are presented in Table 4. On control floors, the alert exhibited a modest sensitivity and high negative predictive value for BG <40 mg/dL. Sensitivity for a BG <40 mg/dL was 76% and 51.5% for BG <60 mg/dL. The alert was developed with a 50% sensitivity for a BG of <60 mg/dL, and the sensitivities calculated on control floors were consistent with the original modeling. The predictive value of an LR classification was 98.2% for not having a BG <40 mg/dL. The predictive value of a positive alert was 9.7% for BG <40 mg/dL.

Test Characteristics and Predictive Values
Variable40 mg/dL Threshold60 mg/dL Threshold
  • NOTE: Abbreviations: BG, blood glucose.

Sensitivity: probability of an alert given BG <40 or 60 mg/dL76.0%51.5%
Specificity: probability of no alert given BG >40 or 60 mg/dL64.6%66.0%
Positive predictive value9.7%26.7%
Negative predictive value (nonalerted patients identified as low risk)98.2%85.0%

There was no significant difference in mortality (P=0.726), transfer to a higher level of care (P=0.296), or LOS between the 2 groups (HR‐I: 5.83 days vs HR‐C: 5.88 days, P=0.664). However, patients with a BG <40 mg/dL had an LOS of 12.2 days (N=45) versus 8.1 days for those without an SH event (N=610), which was statistically significant (P=0.005). There was no increase in the incidence of BG >299 mg/dL in the HR‐I versus HR‐C groups (P=0.53).

Nurse‐physician satisfaction with the alert process was evaluated using a collaboration scale completed after each alert.[8] Of the 195 hypoglycemia alerts, there were 167 (85.6%) nurse and 25 (12.8%) physician collaboration scales completed. Scores were similar among nurses (average 1.52) and physicians (average 1.72), reflecting positive experiences with collaboration. Orders were changed in 40.7% HR‐I patients in response to the collaboration, but in only 20.5% of HR‐C patients after the initial BG of <90 mg/dL occurred. A change in orders constituted a modification consistent with lowering the risk of hypoglycemia and included discontinuing an oral antidiabetic agent, lowering the dose of insulin, and rarely the addition of dextrose‐containing fluids. The most common change in orders was a reduction in the total dose of insulin. A difference in orders changed was partially explained by the collaboration score; a 1‐unit increase in the score correlated to an odds ratio of 2.10 that the orders would be changed (P=0.002).

DISCUSSION

Hospitals are accountable for safe and effective care of patients with hyperglycemia, which includes prevention of medication‐induced hypoglycemia. We have developed a predictive informatics hypoglycemia risk alert that, when tested in a real‐world situation, significantly reduced the rate of SH in hospitalized patients without increasing severe hyperglycemia. The alert algorithm correctly identified patients who were at high risk for hypoglycemia and allowed caretakers the opportunity to lower that risk. The positive predictive value of the alert was low but acceptable at 9.7%, owing to the overall low rate of hypoglycemia in the patient population.

The alert model tested involved 3 components for success: the automated alert, trained charge nurse responders, and an interaction between the nurse responder and the care provider. HR‐I patients were interviewed and assessed for problems associated with oral intake, dietary habits, medication compliance, and hypoglycemia at home prior to communicating with physicians. The extensive training and proficiency in patient assessment and SBAR communication process required by nurses was paramount in the success of the alert. However, the alert provided a definitive risk assessment that was actionable, versus more global instruction, which has not had the same impact in risk reduction. Based on feedback collected from nurses at the study end, they felt the alert process was within their scope of practice and was not unduly burdensome. They also found that the training in diabetes management and SBAR communication techniques, in addition to the alert system, were useful in protecting patients from medication harm.

Physicians for HR‐C patients missed many opportunities to effectively intervene and thereby reduce the likelihood of an SH event. Our assumption is that the clinicians did not ascertain the risk of SH, which was reflected by the fact that orders were changed in 40.7% of HR‐I patients versus only 20.5% in the HR‐C group. Having alerts go directly to nurses rather than physicians permitted inclusion of additional information, such as caloric intake and testing schedules, so that changes in orders would have greater context, and the importance of mild hypoglycemia would not be overlooked.[16] Glycemic control is challenging for providers in the inpatient setting, as there is little time to test and titrate doses of insulin to achieve control. Tight glycemic control has become the primary focus of diabetes management in the outpatient setting to reduce long‐term risks of microvascular complications.[17, 18] However, establishing glycemic targets in the inpatient setting has been difficult because the risk for hypoglycemia increases with tighter control.[19, 20] Inpatient hypoglycemia has been associated with increased mortality, particularly in critically ill patients.[21, 22] Many factors contribute to hypoglycemia including low creatinine clearance, low body weight, untested insulin doses, errors in insulin administration, unexpected dietary changes, changes in medications affecting BG levels, poor communication during times of patient transfer to different care teams, and poor coordination of BG testing with insulin administration at meal times. A multifaceted approach aimed at improving both clinician and nurse awareness, and providing real‐time risk assessment is clearly required to insure patient safety.[6, 13, 23, 24]

There are significant economic benefits to avoiding SH in the hospital given the adverse outcomes associated with HACs and the extra cost associated with these conditions. In hospitalized patients, hypoglycemia worsens outcomes leading to higher costs due to longer LOS (by 3 days), higher inpatient charges (38.9%), and higher risk of discharge to a skilled nursing facility.[1, 3, 25, 26] Conversely, improved glycemic control can reduce surgical site infections, perioperative morbidity, and hospital LOS.[27] The high prevalence of insulin use among inpatients, many of whom have high‐risk characteristics, creates a milieu for both hyper‐ and hypoglycemia. Other groups have described a drop in hypoglycemia rates related to the use of standardized diabetes order sets and nurse and physician education, but this is the first study that used informatics in a prospective manner to identify patients who are at high risk for developing hypoglycemia and then specifically targeted those patients.[28] The alert process was modeled after a similar alert developed in our institution for identifying medicine patients at risk for sepsis.[29] Given the paucity of data related to inpatient glycemia risk reduction, this study is particularly relevant for improving patient safety.

The major limitation of this study is that it was not randomized at the patient level. Patients were assigned to intervention and control groups based on their occupancy on specific hospital floors to avoid treatment bias. Bias was assessed due to this nonrandom assignment by comparing demographic and clinical factors of HR patients between intervention and control floors, and found significant differences in HbA1c and admitting diagnosis. As the control group had lower HbA1c values than the intervention group, and it is known from the Diabetes Control and Complications Trial and Action to Control Cardiovascular Risk in Diabetes trial that lower HbA1c increases the risk of hypoglycemia, our results may be biased by the level of glucose control on admission.[30, 31] Admitting diagnoses differed significantly between intervention and control patients as did the Charlson Comorbidity Index score; however, the hypoglycemia alert system does not include patient diagnoses or comorbidities, and as such provided equipoise with regard to risk reduction regardless of presenting illness. This study included trained nurses, which may be beyond the scope of every institution and thereby limit the effectiveness of the alert in reducing risk. However, as a result of this study, the alert was expanded to other acute care floors at our hospital as well as other hospitals in the Barnes‐Jewish Hospital system.

In summary, this study showed a 68% decrease in episodes of SH in a high‐risk patient cohort on diabetic medications using a hypoglycemia alert system. The results of this study demonstrate the validity of a systems‐based approach to reduce SH in high‐risk inpatients.

Disclosures

This work was funded by the Barnes‐Jewish Hospital Foundation The authors report no conflicts of interest.

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References
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  2. Kagansky N, Levy S, Rimon E, et al. Hypoglycemia as a predictor of mortality in hospitalized elderly patients. Arch Intern Med. 2003;163:18251829.
  3. Turchin A, Matheny ME, Shubina M, Scanlon JV, Greenwood B, Pendergrass ML. Hypoglycemia and clinical outcomes in patients with diabetes hospitalized in the general ward. Diabetes Care. 2009;32:11531157.
  4. Desouza C, Salazar H, Cheong B, Murgo J, Fonseca V. Association of hypoglycemia and cardiac ischemia: a study based on continuous glucose monitoring. Diabetes Care. 2003;26:14851489.
  5. Schwartz AV, Vittinghoff E, Sellmeyer DE, et al. Diabetes‐related complications, glycemic control, and falls in older adults. Diabetes Care. 2008;31:391396.
  6. Deal EN, Liu A, Wise LL, Honick KA, Tobin GS. Inpatient insulin orders: are patients getting what is prescribed? J Hosp Med. 2011;9:526529.
  7. Elliot MB, Schafers SJ, McGill JM, Tobin GS. Prediction and prevention of treatment‐related inpatient hypoglycemia. J Diabetes Sci Technol. 2012;6:302309.
  8. Baggs JG, Schmitt MH. Collaboration between nurses and physicians. Image J Nurs Sch. 1988;20:145149.
  9. Goldberg PA, Bozzo JE, Thomas PG, et al. Glucometrics—assessing the quality of inpatient glucose management. Diabetes Technol Ther. 2005;8:560569.
  10. ACE/ADA Task Force on Inpatient Diabetes. American College of Endocrinology and American Diabetes Association consensus statement on inpatient diabetes and glycemic control. Diabetes Care. 2006;29:19551962.
  11. Moghissi ES, Korytkowski MT, DiNardo M, et al. American Association of Clinical Endocrinologists and American Diabetes Association consensus statement on inpatient glycemic control. Endocr Pract. 2009;15:353369.
  12. Kesten KS. Role‐play using SBAR technique to improve observed communication skills in senior nursing students. J Nurs Educ. 2011;50:7987.
  13. SHM Glycemic Control Task Force. Workbook for improvement: improving glycemic control, preventing hypoglycemia, and optimizing care of the inpatient with hyperglycemia and diabetes. Society of Hospital Medicine website, Glycemic Control Quality Improvement Resource Room. Available at: http://www.hospitalmedicine.org. Accessed on February 12, 2011.
  14. Thomas P, Inzucchi SE. An internet service supporting quality assessment of inpatient glycemic control. J Diabetes Sci and Technol. 2008;2:402408.
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  17. The Diabetes Control and Complications Trial Research Group. The effect of intensive treatment of diabetes on the development and progression of long‐term complications in insulin‐dependent diabetes mellitus. N Engl J Med. 1993;329:977986.
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  20. Cryer PE. Hypoglycemia: still the limiting factor in the glycemic management of diabetes. Endocr Pract. 2008;14:750756.
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Insulin therapy in the hospital setting can cause hypoglycemia, which may lead to increased mortality and length of stay (LOS).[1, 2, 3] Hypoglycemia is associated with cardiovascular, cerebrovascular, and patient fall events.[4, 5] The Centers for Medicare and Medicaid Services have designated both severe hypoglycemia (SH) with harm and diabetic ketoacidosis as hospital acquired conditions (HAC) or never events. The Society for Hospital Medicine (SHM) defines SH in the hospital as a blood glucose (BG) <40 mg/dL. Minimizing episodes of SH is important for patient health outcomes, patient safety, and for healthcare facilities' safety metrics.

Many factors contribute to SH including excessive insulin doses, medication errors, inappropriate timing of insulin doses with food intake, changes in nutritional status, impaired renal function, and changes in medications such as steroids.[6] As part of a multiyear project in patient safety, an inpatient hypoglycemia alert algorithm was developed based on a multivariate analysis of individual patient demographic, pharmacy, laboratory, and glucometric data. The algorithm was previously shown to have a 75% sensitivity to predict episodes of SH.[7] In this study, we tested whether a predictive real‐time informatics hypoglycemia alert based on the tested algorithm, along with trained nurses, would result in a decreased frequency of SH events compared to usual care. We hypothesized that this alert would result in a reduction of SH events in those patients at high risk for hypoglycemia.

METHODS

Study Design and Population

This prospective cohort‐intervention study involved inpatients admitted to Barnes‐Jewish Hospital in St. Louis, Missouri, the academic hospital of Washington University School of Medicine (WUSM), from August 2011 through December 2011. Fourteen floors, including 10 internal medicine and 4 cardiology medicine floors, were selected based upon a high frequency of severe hypoglycemic events noted in 2010. Six of the internal medicine floors were designated as intervention floors, and 8 were designated as control floors, including the 4 cardiology units. The study population consisted of patients receiving diabetic medications on study floors who had a BG <90 mg/dL during their hospital stay (Figure 1). The study was approved by the WUSM institutional review board and included a waiver of consent for individual patients.

Figure 1
Study enrollment.

The pharmacy informatics system was programmed with the previously developed hypoglycemia alert to prospectively identify those patients at high risk of hypoglycemia based on real‐time patient information.[7] Patients were identified as high risk on study floors if insulin or an oral antihyperglycemic agent was prescribed and if their hypoglycemia informatics generated risk score was >35 within 24 hours of having a capillary or venous BG<90 mg/dL. The risk score of 35 corresponded to a 50% sensitivity for a subsequent BG <60 mg/dL and a 75% sensitivity for a BG <40 mg/dL. Patients who generated an alert once during their hospital stay were assigned to 1 of 3 categories based on their admission division and risk score: high‐risk intervention (HR‐I), high‐risk control (HR‐C), or low risk (LR). LR patients also had a BG <90 mg/dL during their stay, but a risk score of <35.

The electronic alert for HR‐I patients was sent by pager to division‐specific charge nurses. Fourteen charge nurses on intervention divisions were trained to assess the alert, interview the patient, identify an alternate dosing strategy, and collaborate with the patient's physicians. HR‐C patients were identified on control divisions based on the same criteria as intervention patients, but no alert was generated. Control patients' charts were reviewed and evaluated upon discharge by the research team‐certified diabetes nurse educator to determine whether the treating physician had identified the SH risk and had changed insulin orders.

Nurses and physicians caring for patients on study divisions provided informed consent to participate in the study. Nurses' satisfaction with the alert process and physician interaction was assessed with a collaboration scale that was completed after each alert (see Supporting Information, Appendix A, in the online version of this article).[8]

Alert Development Process

The alert equation algorithm was developed at Barnes‐Jewish Hospital after a retrospective analysis of hospital glucometric data, including capillary and venous BG measurements, and demographic and pharmacy data over a 6‐month time period.[9] The analysis identified factors that were independently associated with hypoglycemia and used these variables in a mathematical model to achieve a 50% sensitivity to predict a subsequent BG of <60 mg/dL and a 75% sensitivity to predict SH.[7] Table 1 outlines the variables in the model and provides the risk‐score equation used to generate an alert.

Variables Identified as Conferring Higher Risk for Hypoglycemia in the Alert and Risk Equation
VariableDescription of Variable
Body weightPatients at a lower weight were at an increased risk. The variable had a linear response, and 3 levels were used to modify the risk equation: <69 kg, 7079 kg, and >80 kg.
Creatinine clearancePatients with a lower creatinine clearance were at an increased risk. This variable had a linear response, and 2 levels were used to modify the risk equation: <48 mL/min or >48 mL/min.
Basal insulin doseIncreased risk was noted at a doses of basal insulin >0.25 U/kg.
Basal‐only dosingDosing of basal insulin without meal‐time insulin conferred increased risk.
Nonstandard insulin therapyThe use of 70/30 insulin was associated with increased risk.
Oral diabetic therapyUse of sulfonylureas was associated with increased risk.
Risk score equation(Value <60)=0.055+1.062 * (Basal <0.25 U/kg)+1.234 * (Basal 0.25 U/kg) & minus;0.294 * (Weight <6069 kg)0.540 * (Weight 7079 kg)0.786 * (Weight 80 kg) & minus;0.389 * (Creatinine Clearance <3847) 0.680 * (Creatinine Clearance 48) 0.239 * (Sliding Yes) 0.556*(Meal Yes)+0.951 * (Sliding and Meal)+0.336 * (Sulfonylurea Yes) Score=100 * (Exp (Value <60)/(1+Exp (Value <60))

The alert used a BG cutoff of 90 mg/dL in accordance with the American College of Endocrinology Hospital Guideline. Although current guidelines from the SHM recommend keeping BG values >100 mg/dL for patient safety, our analysis found that the cutoff of 90 mg/dL had better sensitivity and specificity than the <100 mg/dL guideline for the risk algorithm.[10, 11]

Nurse and Physician Training

Charge nurses received 5 hours of hyperglycemia management training in 3 sessions utilizing a structured curriculum. Session 1 included a pretest followed by diabetes management education. Session 2 was devoted to an interactive workshop utilizing case‐based scenarios of diabetes management problems and hypoglycemia prevention. The final session provided instructions on the electronic alert communication process. Nurses were empowered with tools for effective communication practices using the situation‐background‐assessment‐recommendation (SBAR) technique.[12]

Physicians, including hospitalists and medicine residents on intervention and control floors, took a pretest, received a 1‐hour lecture, and completed the same curriculum of case‐based scenarios in an online self‐directed learning module. Physicians did not receive SBAR training. Both nurses and physicians received pocket cards with insulin management guidelines developed by our research team to ensure that all clinicians had common prescribing practices.[13]

Outcomes

The primary outcome was the incidence of SH occurring in HR‐I versus HR‐C patients. Secondary outcomes included: episodes of SH in LR study patients, incidence of BG<60 mg/dL frequency of transfer to a higher level of care, incidence of severe hyperglycemia defined as BG >299 mg/dL, frequency that high‐risk patient's orders were changed to reduce hypoglycemia risk in response to the alert‐intervention process, LOS, mortality, and a nurse‐physician collaboration scale score.[14]

Statistical Analysis

Demographic and clinical metrics were compared between HR‐I and HR‐C patients to evaluate potential sources of bias. These included age, weight, serum creatinine, creatinine clearance (measured by Cockcroft‐Gault), hemoglobin A1c (HbA1c) if available, LOS, gender, admitting diagnosis, type of diabetes, and Charlson Comorbidity Index score. The alert risk‐score was also compared between intervention and control floors. Two‐tailed t tests assessed differences between the study groups on normally distributed variables, whereas Wilcoxon rank sum tests were used for non‐normally distributed variables, and 2 tests were used for categorical variables. Two‐tailed Fisher exact tests compared the prevalence of hypoglycemia thresholds between the study groups. 2 analysis was used to compare the proportion of patients who experienced a BG >299 mg/dL between intervention and controls and the proportion of orders changed in HR‐I versus HR‐C patients. Logistic regression was used to test the association of nurse collaboration score with the likelihood of orders being changed.

Based on previous research, we estimated a 48% rate of hypoglycemia <60 mg/dL in HR‐C patients on control floors.[7] We calculated a sample size of 195 subjects in each high‐risk group as the number needed for the intervention to produce a clinically meaningful reduction in hypoglycemia of 25% on the intervention floor compared to the control floors with 90% power.

RESULTS

Study Cohort and Patient Characteristics

One hundred ninety‐five patients who met criteria for high‐risk status were enrolled on HR‐I floors and HR‐C floors for a total of 390 high‐risk patients. During the same time period, 265 LR patients were identified on intervention (153 patients) and control (112 patients) floors. The HR‐I patients were similar to the HR‐C patients by baseline demographics, as shown in Table 2. HbA1c was not available on all patients, but the mean HbA1c in the HR‐I group was 7.93% versus 7.40% in the HR‐C group (P=0.048). The Charlson Comorbidity Index score was significantly different between the high‐risk groups (HR‐I: 6.48 vs HR‐C: 7.48, P=0.002), indicating that the HR‐C patients had more comorbidities.[15] There were significant differences in 2 of the 3 most common admitting diagnoses between groups, with more HR‐C patients admitted for circulatory system diseases (HR‐C: 22.3% vs HR‐I: 4.4%, P=0.001), and more HR‐I patients admitted for digestive system diseases (HR‐I: 13.7% vs HR‐C: 3.3%, P<0.001). The proportion of patients with preexisting type 2 diabetes did not differ by intervention status (HR‐I: 89.8% vs HR‐C: 92.0%, P=0.462).

Baseline Patient Characteristics
DemographicHR‐I, Mean SD/Frequency (%), N=195HR‐C, Mean, SD/Frequency (%), N=195Low Risk, Mean, SD/Frequency (%), N=265P Value*
  • NOTE: Abbreviations: HR‐C, high‐risk control; HR‐I, high‐risk intervention. *HR‐I vs HR‐C.

Age, y60.2 (15.1)60.3 (16.9)61.0 (13.8)0.940
Weight, kg84.9 (31.9)80.8 (26.6)93.6 (28.7)0.173
Serum creatinine, mg/dL2.06 (2.56)2.03 (1.87)1.89 (2.17)0.910
Creatinine clearance, mL/min50.6 (29.8)45.4 (27.1)55.5 (29.3)0.077
Hemoglobin A1c, n (%) with data7.93 (2.46), n=130 (67%)7.40 (1.75), n=115 (59%)6.65 (2.05), n=152 (57%)0.048
Risk score52 (11)54 (11)26 (6)0.111
Length of stay, median, d5.835.885.790.664
Male gender84 (43.1%)98 (50.3%)145 (54.7%)0.155
Type 2 diabetes167 (89.8%)172 (92.0%)219 (95.6%)0.462
Charlson Comorbidity Index score6.48 (3.06)7.48 (3.28)6.66 (3.24)0.002
Admit diagnosis endocrine, nutritional, metabolic diseases, and immunity disorders (codes 240279)17 (9.3%)10 (5.4%)11 (4.3%)0.153
Admit diagnosis disease of circulatory system (codes 390459)8 (4.4%)41 (22.3%)26 (10.1%)<0.001
Admit diagnosis disease of digestive system (codes 520579)25 (13.7%)6 (3.3%)27 (10.5%)<0.001
Admit diagnosis diseases of the genitourinary system (codes 580629)6 (3.3%)4 (2.2%)15 (5.8%)0.510
Admit diagnosis reported only as signs, symptoms, or ill‐defined conditions (codes 780799)77 (42.3%)92 (50.0%)121 (46.9%)0.140

Study Outcomes

The rate of hypoglycemia was compared between 195 HR‐I and 195 HR‐C patients, and it should be noted that each patient could generate only 1 episode of hypoglycemia during an admission. As shown in Table 3, the incidence of a BG <60 mg/dL was significantly lower in the HR‐I patients versus the HR‐C patients (13.3% vs 26.7%, P=0.002) as was the incidence of a BG <40 mg/dL (3.1% HR‐I vs 9.7% HR‐C, P=0.012). This represents a decrease of 50% in moderate hypoglycemia (BG <60 mg/dL) and a decrease of 68% in SH (BG <40 mg/dL) between HR‐I and HR‐C patients. Severe hyperglycemia occurrences were not significantly different between intervention and control floors at 28% each.

Rate of Hypoglycemia in Alerted Patients
Alerted Patients Glucose ThresholdHR‐I (%), N=195HR‐C (%), N=195Low Risk (%), N=265P Value*
  • NOTE: Abbreviations: BG, blood glucose; HR‐C, high‐risk control; HR‐I, high‐risk intervention. *HR‐I vs HR‐C.

With BG <40 mg/dL6 (3.1%)19 (9.7%)10 (3.8%)0.012
With BG <60 mg/dL26 (13.3%)51 (26.7%)50 (18.9%)0.002
With BG >299 mg/dL53 (28.0%)53 (27.9%)29 (11.9%)0.974

The sensitivity, specificity, and predictive values of the alert for BG thresholds of <40 mg/dL and <60 mg/dL are presented in Table 4. On control floors, the alert exhibited a modest sensitivity and high negative predictive value for BG <40 mg/dL. Sensitivity for a BG <40 mg/dL was 76% and 51.5% for BG <60 mg/dL. The alert was developed with a 50% sensitivity for a BG of <60 mg/dL, and the sensitivities calculated on control floors were consistent with the original modeling. The predictive value of an LR classification was 98.2% for not having a BG <40 mg/dL. The predictive value of a positive alert was 9.7% for BG <40 mg/dL.

Test Characteristics and Predictive Values
Variable40 mg/dL Threshold60 mg/dL Threshold
  • NOTE: Abbreviations: BG, blood glucose.

Sensitivity: probability of an alert given BG <40 or 60 mg/dL76.0%51.5%
Specificity: probability of no alert given BG >40 or 60 mg/dL64.6%66.0%
Positive predictive value9.7%26.7%
Negative predictive value (nonalerted patients identified as low risk)98.2%85.0%

There was no significant difference in mortality (P=0.726), transfer to a higher level of care (P=0.296), or LOS between the 2 groups (HR‐I: 5.83 days vs HR‐C: 5.88 days, P=0.664). However, patients with a BG <40 mg/dL had an LOS of 12.2 days (N=45) versus 8.1 days for those without an SH event (N=610), which was statistically significant (P=0.005). There was no increase in the incidence of BG >299 mg/dL in the HR‐I versus HR‐C groups (P=0.53).

Nurse‐physician satisfaction with the alert process was evaluated using a collaboration scale completed after each alert.[8] Of the 195 hypoglycemia alerts, there were 167 (85.6%) nurse and 25 (12.8%) physician collaboration scales completed. Scores were similar among nurses (average 1.52) and physicians (average 1.72), reflecting positive experiences with collaboration. Orders were changed in 40.7% HR‐I patients in response to the collaboration, but in only 20.5% of HR‐C patients after the initial BG of <90 mg/dL occurred. A change in orders constituted a modification consistent with lowering the risk of hypoglycemia and included discontinuing an oral antidiabetic agent, lowering the dose of insulin, and rarely the addition of dextrose‐containing fluids. The most common change in orders was a reduction in the total dose of insulin. A difference in orders changed was partially explained by the collaboration score; a 1‐unit increase in the score correlated to an odds ratio of 2.10 that the orders would be changed (P=0.002).

DISCUSSION

Hospitals are accountable for safe and effective care of patients with hyperglycemia, which includes prevention of medication‐induced hypoglycemia. We have developed a predictive informatics hypoglycemia risk alert that, when tested in a real‐world situation, significantly reduced the rate of SH in hospitalized patients without increasing severe hyperglycemia. The alert algorithm correctly identified patients who were at high risk for hypoglycemia and allowed caretakers the opportunity to lower that risk. The positive predictive value of the alert was low but acceptable at 9.7%, owing to the overall low rate of hypoglycemia in the patient population.

The alert model tested involved 3 components for success: the automated alert, trained charge nurse responders, and an interaction between the nurse responder and the care provider. HR‐I patients were interviewed and assessed for problems associated with oral intake, dietary habits, medication compliance, and hypoglycemia at home prior to communicating with physicians. The extensive training and proficiency in patient assessment and SBAR communication process required by nurses was paramount in the success of the alert. However, the alert provided a definitive risk assessment that was actionable, versus more global instruction, which has not had the same impact in risk reduction. Based on feedback collected from nurses at the study end, they felt the alert process was within their scope of practice and was not unduly burdensome. They also found that the training in diabetes management and SBAR communication techniques, in addition to the alert system, were useful in protecting patients from medication harm.

Physicians for HR‐C patients missed many opportunities to effectively intervene and thereby reduce the likelihood of an SH event. Our assumption is that the clinicians did not ascertain the risk of SH, which was reflected by the fact that orders were changed in 40.7% of HR‐I patients versus only 20.5% in the HR‐C group. Having alerts go directly to nurses rather than physicians permitted inclusion of additional information, such as caloric intake and testing schedules, so that changes in orders would have greater context, and the importance of mild hypoglycemia would not be overlooked.[16] Glycemic control is challenging for providers in the inpatient setting, as there is little time to test and titrate doses of insulin to achieve control. Tight glycemic control has become the primary focus of diabetes management in the outpatient setting to reduce long‐term risks of microvascular complications.[17, 18] However, establishing glycemic targets in the inpatient setting has been difficult because the risk for hypoglycemia increases with tighter control.[19, 20] Inpatient hypoglycemia has been associated with increased mortality, particularly in critically ill patients.[21, 22] Many factors contribute to hypoglycemia including low creatinine clearance, low body weight, untested insulin doses, errors in insulin administration, unexpected dietary changes, changes in medications affecting BG levels, poor communication during times of patient transfer to different care teams, and poor coordination of BG testing with insulin administration at meal times. A multifaceted approach aimed at improving both clinician and nurse awareness, and providing real‐time risk assessment is clearly required to insure patient safety.[6, 13, 23, 24]

There are significant economic benefits to avoiding SH in the hospital given the adverse outcomes associated with HACs and the extra cost associated with these conditions. In hospitalized patients, hypoglycemia worsens outcomes leading to higher costs due to longer LOS (by 3 days), higher inpatient charges (38.9%), and higher risk of discharge to a skilled nursing facility.[1, 3, 25, 26] Conversely, improved glycemic control can reduce surgical site infections, perioperative morbidity, and hospital LOS.[27] The high prevalence of insulin use among inpatients, many of whom have high‐risk characteristics, creates a milieu for both hyper‐ and hypoglycemia. Other groups have described a drop in hypoglycemia rates related to the use of standardized diabetes order sets and nurse and physician education, but this is the first study that used informatics in a prospective manner to identify patients who are at high risk for developing hypoglycemia and then specifically targeted those patients.[28] The alert process was modeled after a similar alert developed in our institution for identifying medicine patients at risk for sepsis.[29] Given the paucity of data related to inpatient glycemia risk reduction, this study is particularly relevant for improving patient safety.

The major limitation of this study is that it was not randomized at the patient level. Patients were assigned to intervention and control groups based on their occupancy on specific hospital floors to avoid treatment bias. Bias was assessed due to this nonrandom assignment by comparing demographic and clinical factors of HR patients between intervention and control floors, and found significant differences in HbA1c and admitting diagnosis. As the control group had lower HbA1c values than the intervention group, and it is known from the Diabetes Control and Complications Trial and Action to Control Cardiovascular Risk in Diabetes trial that lower HbA1c increases the risk of hypoglycemia, our results may be biased by the level of glucose control on admission.[30, 31] Admitting diagnoses differed significantly between intervention and control patients as did the Charlson Comorbidity Index score; however, the hypoglycemia alert system does not include patient diagnoses or comorbidities, and as such provided equipoise with regard to risk reduction regardless of presenting illness. This study included trained nurses, which may be beyond the scope of every institution and thereby limit the effectiveness of the alert in reducing risk. However, as a result of this study, the alert was expanded to other acute care floors at our hospital as well as other hospitals in the Barnes‐Jewish Hospital system.

In summary, this study showed a 68% decrease in episodes of SH in a high‐risk patient cohort on diabetic medications using a hypoglycemia alert system. The results of this study demonstrate the validity of a systems‐based approach to reduce SH in high‐risk inpatients.

Disclosures

This work was funded by the Barnes‐Jewish Hospital Foundation The authors report no conflicts of interest.

Insulin therapy in the hospital setting can cause hypoglycemia, which may lead to increased mortality and length of stay (LOS).[1, 2, 3] Hypoglycemia is associated with cardiovascular, cerebrovascular, and patient fall events.[4, 5] The Centers for Medicare and Medicaid Services have designated both severe hypoglycemia (SH) with harm and diabetic ketoacidosis as hospital acquired conditions (HAC) or never events. The Society for Hospital Medicine (SHM) defines SH in the hospital as a blood glucose (BG) <40 mg/dL. Minimizing episodes of SH is important for patient health outcomes, patient safety, and for healthcare facilities' safety metrics.

Many factors contribute to SH including excessive insulin doses, medication errors, inappropriate timing of insulin doses with food intake, changes in nutritional status, impaired renal function, and changes in medications such as steroids.[6] As part of a multiyear project in patient safety, an inpatient hypoglycemia alert algorithm was developed based on a multivariate analysis of individual patient demographic, pharmacy, laboratory, and glucometric data. The algorithm was previously shown to have a 75% sensitivity to predict episodes of SH.[7] In this study, we tested whether a predictive real‐time informatics hypoglycemia alert based on the tested algorithm, along with trained nurses, would result in a decreased frequency of SH events compared to usual care. We hypothesized that this alert would result in a reduction of SH events in those patients at high risk for hypoglycemia.

METHODS

Study Design and Population

This prospective cohort‐intervention study involved inpatients admitted to Barnes‐Jewish Hospital in St. Louis, Missouri, the academic hospital of Washington University School of Medicine (WUSM), from August 2011 through December 2011. Fourteen floors, including 10 internal medicine and 4 cardiology medicine floors, were selected based upon a high frequency of severe hypoglycemic events noted in 2010. Six of the internal medicine floors were designated as intervention floors, and 8 were designated as control floors, including the 4 cardiology units. The study population consisted of patients receiving diabetic medications on study floors who had a BG <90 mg/dL during their hospital stay (Figure 1). The study was approved by the WUSM institutional review board and included a waiver of consent for individual patients.

Figure 1
Study enrollment.

The pharmacy informatics system was programmed with the previously developed hypoglycemia alert to prospectively identify those patients at high risk of hypoglycemia based on real‐time patient information.[7] Patients were identified as high risk on study floors if insulin or an oral antihyperglycemic agent was prescribed and if their hypoglycemia informatics generated risk score was >35 within 24 hours of having a capillary or venous BG<90 mg/dL. The risk score of 35 corresponded to a 50% sensitivity for a subsequent BG <60 mg/dL and a 75% sensitivity for a BG <40 mg/dL. Patients who generated an alert once during their hospital stay were assigned to 1 of 3 categories based on their admission division and risk score: high‐risk intervention (HR‐I), high‐risk control (HR‐C), or low risk (LR). LR patients also had a BG <90 mg/dL during their stay, but a risk score of <35.

The electronic alert for HR‐I patients was sent by pager to division‐specific charge nurses. Fourteen charge nurses on intervention divisions were trained to assess the alert, interview the patient, identify an alternate dosing strategy, and collaborate with the patient's physicians. HR‐C patients were identified on control divisions based on the same criteria as intervention patients, but no alert was generated. Control patients' charts were reviewed and evaluated upon discharge by the research team‐certified diabetes nurse educator to determine whether the treating physician had identified the SH risk and had changed insulin orders.

Nurses and physicians caring for patients on study divisions provided informed consent to participate in the study. Nurses' satisfaction with the alert process and physician interaction was assessed with a collaboration scale that was completed after each alert (see Supporting Information, Appendix A, in the online version of this article).[8]

Alert Development Process

The alert equation algorithm was developed at Barnes‐Jewish Hospital after a retrospective analysis of hospital glucometric data, including capillary and venous BG measurements, and demographic and pharmacy data over a 6‐month time period.[9] The analysis identified factors that were independently associated with hypoglycemia and used these variables in a mathematical model to achieve a 50% sensitivity to predict a subsequent BG of <60 mg/dL and a 75% sensitivity to predict SH.[7] Table 1 outlines the variables in the model and provides the risk‐score equation used to generate an alert.

Variables Identified as Conferring Higher Risk for Hypoglycemia in the Alert and Risk Equation
VariableDescription of Variable
Body weightPatients at a lower weight were at an increased risk. The variable had a linear response, and 3 levels were used to modify the risk equation: <69 kg, 7079 kg, and >80 kg.
Creatinine clearancePatients with a lower creatinine clearance were at an increased risk. This variable had a linear response, and 2 levels were used to modify the risk equation: <48 mL/min or >48 mL/min.
Basal insulin doseIncreased risk was noted at a doses of basal insulin >0.25 U/kg.
Basal‐only dosingDosing of basal insulin without meal‐time insulin conferred increased risk.
Nonstandard insulin therapyThe use of 70/30 insulin was associated with increased risk.
Oral diabetic therapyUse of sulfonylureas was associated with increased risk.
Risk score equation(Value <60)=0.055+1.062 * (Basal <0.25 U/kg)+1.234 * (Basal 0.25 U/kg) & minus;0.294 * (Weight <6069 kg)0.540 * (Weight 7079 kg)0.786 * (Weight 80 kg) & minus;0.389 * (Creatinine Clearance <3847) 0.680 * (Creatinine Clearance 48) 0.239 * (Sliding Yes) 0.556*(Meal Yes)+0.951 * (Sliding and Meal)+0.336 * (Sulfonylurea Yes) Score=100 * (Exp (Value <60)/(1+Exp (Value <60))

The alert used a BG cutoff of 90 mg/dL in accordance with the American College of Endocrinology Hospital Guideline. Although current guidelines from the SHM recommend keeping BG values >100 mg/dL for patient safety, our analysis found that the cutoff of 90 mg/dL had better sensitivity and specificity than the <100 mg/dL guideline for the risk algorithm.[10, 11]

Nurse and Physician Training

Charge nurses received 5 hours of hyperglycemia management training in 3 sessions utilizing a structured curriculum. Session 1 included a pretest followed by diabetes management education. Session 2 was devoted to an interactive workshop utilizing case‐based scenarios of diabetes management problems and hypoglycemia prevention. The final session provided instructions on the electronic alert communication process. Nurses were empowered with tools for effective communication practices using the situation‐background‐assessment‐recommendation (SBAR) technique.[12]

Physicians, including hospitalists and medicine residents on intervention and control floors, took a pretest, received a 1‐hour lecture, and completed the same curriculum of case‐based scenarios in an online self‐directed learning module. Physicians did not receive SBAR training. Both nurses and physicians received pocket cards with insulin management guidelines developed by our research team to ensure that all clinicians had common prescribing practices.[13]

Outcomes

The primary outcome was the incidence of SH occurring in HR‐I versus HR‐C patients. Secondary outcomes included: episodes of SH in LR study patients, incidence of BG<60 mg/dL frequency of transfer to a higher level of care, incidence of severe hyperglycemia defined as BG >299 mg/dL, frequency that high‐risk patient's orders were changed to reduce hypoglycemia risk in response to the alert‐intervention process, LOS, mortality, and a nurse‐physician collaboration scale score.[14]

Statistical Analysis

Demographic and clinical metrics were compared between HR‐I and HR‐C patients to evaluate potential sources of bias. These included age, weight, serum creatinine, creatinine clearance (measured by Cockcroft‐Gault), hemoglobin A1c (HbA1c) if available, LOS, gender, admitting diagnosis, type of diabetes, and Charlson Comorbidity Index score. The alert risk‐score was also compared between intervention and control floors. Two‐tailed t tests assessed differences between the study groups on normally distributed variables, whereas Wilcoxon rank sum tests were used for non‐normally distributed variables, and 2 tests were used for categorical variables. Two‐tailed Fisher exact tests compared the prevalence of hypoglycemia thresholds between the study groups. 2 analysis was used to compare the proportion of patients who experienced a BG >299 mg/dL between intervention and controls and the proportion of orders changed in HR‐I versus HR‐C patients. Logistic regression was used to test the association of nurse collaboration score with the likelihood of orders being changed.

Based on previous research, we estimated a 48% rate of hypoglycemia <60 mg/dL in HR‐C patients on control floors.[7] We calculated a sample size of 195 subjects in each high‐risk group as the number needed for the intervention to produce a clinically meaningful reduction in hypoglycemia of 25% on the intervention floor compared to the control floors with 90% power.

RESULTS

Study Cohort and Patient Characteristics

One hundred ninety‐five patients who met criteria for high‐risk status were enrolled on HR‐I floors and HR‐C floors for a total of 390 high‐risk patients. During the same time period, 265 LR patients were identified on intervention (153 patients) and control (112 patients) floors. The HR‐I patients were similar to the HR‐C patients by baseline demographics, as shown in Table 2. HbA1c was not available on all patients, but the mean HbA1c in the HR‐I group was 7.93% versus 7.40% in the HR‐C group (P=0.048). The Charlson Comorbidity Index score was significantly different between the high‐risk groups (HR‐I: 6.48 vs HR‐C: 7.48, P=0.002), indicating that the HR‐C patients had more comorbidities.[15] There were significant differences in 2 of the 3 most common admitting diagnoses between groups, with more HR‐C patients admitted for circulatory system diseases (HR‐C: 22.3% vs HR‐I: 4.4%, P=0.001), and more HR‐I patients admitted for digestive system diseases (HR‐I: 13.7% vs HR‐C: 3.3%, P<0.001). The proportion of patients with preexisting type 2 diabetes did not differ by intervention status (HR‐I: 89.8% vs HR‐C: 92.0%, P=0.462).

Baseline Patient Characteristics
DemographicHR‐I, Mean SD/Frequency (%), N=195HR‐C, Mean, SD/Frequency (%), N=195Low Risk, Mean, SD/Frequency (%), N=265P Value*
  • NOTE: Abbreviations: HR‐C, high‐risk control; HR‐I, high‐risk intervention. *HR‐I vs HR‐C.

Age, y60.2 (15.1)60.3 (16.9)61.0 (13.8)0.940
Weight, kg84.9 (31.9)80.8 (26.6)93.6 (28.7)0.173
Serum creatinine, mg/dL2.06 (2.56)2.03 (1.87)1.89 (2.17)0.910
Creatinine clearance, mL/min50.6 (29.8)45.4 (27.1)55.5 (29.3)0.077
Hemoglobin A1c, n (%) with data7.93 (2.46), n=130 (67%)7.40 (1.75), n=115 (59%)6.65 (2.05), n=152 (57%)0.048
Risk score52 (11)54 (11)26 (6)0.111
Length of stay, median, d5.835.885.790.664
Male gender84 (43.1%)98 (50.3%)145 (54.7%)0.155
Type 2 diabetes167 (89.8%)172 (92.0%)219 (95.6%)0.462
Charlson Comorbidity Index score6.48 (3.06)7.48 (3.28)6.66 (3.24)0.002
Admit diagnosis endocrine, nutritional, metabolic diseases, and immunity disorders (codes 240279)17 (9.3%)10 (5.4%)11 (4.3%)0.153
Admit diagnosis disease of circulatory system (codes 390459)8 (4.4%)41 (22.3%)26 (10.1%)<0.001
Admit diagnosis disease of digestive system (codes 520579)25 (13.7%)6 (3.3%)27 (10.5%)<0.001
Admit diagnosis diseases of the genitourinary system (codes 580629)6 (3.3%)4 (2.2%)15 (5.8%)0.510
Admit diagnosis reported only as signs, symptoms, or ill‐defined conditions (codes 780799)77 (42.3%)92 (50.0%)121 (46.9%)0.140

Study Outcomes

The rate of hypoglycemia was compared between 195 HR‐I and 195 HR‐C patients, and it should be noted that each patient could generate only 1 episode of hypoglycemia during an admission. As shown in Table 3, the incidence of a BG <60 mg/dL was significantly lower in the HR‐I patients versus the HR‐C patients (13.3% vs 26.7%, P=0.002) as was the incidence of a BG <40 mg/dL (3.1% HR‐I vs 9.7% HR‐C, P=0.012). This represents a decrease of 50% in moderate hypoglycemia (BG <60 mg/dL) and a decrease of 68% in SH (BG <40 mg/dL) between HR‐I and HR‐C patients. Severe hyperglycemia occurrences were not significantly different between intervention and control floors at 28% each.

Rate of Hypoglycemia in Alerted Patients
Alerted Patients Glucose ThresholdHR‐I (%), N=195HR‐C (%), N=195Low Risk (%), N=265P Value*
  • NOTE: Abbreviations: BG, blood glucose; HR‐C, high‐risk control; HR‐I, high‐risk intervention. *HR‐I vs HR‐C.

With BG <40 mg/dL6 (3.1%)19 (9.7%)10 (3.8%)0.012
With BG <60 mg/dL26 (13.3%)51 (26.7%)50 (18.9%)0.002
With BG >299 mg/dL53 (28.0%)53 (27.9%)29 (11.9%)0.974

The sensitivity, specificity, and predictive values of the alert for BG thresholds of <40 mg/dL and <60 mg/dL are presented in Table 4. On control floors, the alert exhibited a modest sensitivity and high negative predictive value for BG <40 mg/dL. Sensitivity for a BG <40 mg/dL was 76% and 51.5% for BG <60 mg/dL. The alert was developed with a 50% sensitivity for a BG of <60 mg/dL, and the sensitivities calculated on control floors were consistent with the original modeling. The predictive value of an LR classification was 98.2% for not having a BG <40 mg/dL. The predictive value of a positive alert was 9.7% for BG <40 mg/dL.

Test Characteristics and Predictive Values
Variable40 mg/dL Threshold60 mg/dL Threshold
  • NOTE: Abbreviations: BG, blood glucose.

Sensitivity: probability of an alert given BG <40 or 60 mg/dL76.0%51.5%
Specificity: probability of no alert given BG >40 or 60 mg/dL64.6%66.0%
Positive predictive value9.7%26.7%
Negative predictive value (nonalerted patients identified as low risk)98.2%85.0%

There was no significant difference in mortality (P=0.726), transfer to a higher level of care (P=0.296), or LOS between the 2 groups (HR‐I: 5.83 days vs HR‐C: 5.88 days, P=0.664). However, patients with a BG <40 mg/dL had an LOS of 12.2 days (N=45) versus 8.1 days for those without an SH event (N=610), which was statistically significant (P=0.005). There was no increase in the incidence of BG >299 mg/dL in the HR‐I versus HR‐C groups (P=0.53).

Nurse‐physician satisfaction with the alert process was evaluated using a collaboration scale completed after each alert.[8] Of the 195 hypoglycemia alerts, there were 167 (85.6%) nurse and 25 (12.8%) physician collaboration scales completed. Scores were similar among nurses (average 1.52) and physicians (average 1.72), reflecting positive experiences with collaboration. Orders were changed in 40.7% HR‐I patients in response to the collaboration, but in only 20.5% of HR‐C patients after the initial BG of <90 mg/dL occurred. A change in orders constituted a modification consistent with lowering the risk of hypoglycemia and included discontinuing an oral antidiabetic agent, lowering the dose of insulin, and rarely the addition of dextrose‐containing fluids. The most common change in orders was a reduction in the total dose of insulin. A difference in orders changed was partially explained by the collaboration score; a 1‐unit increase in the score correlated to an odds ratio of 2.10 that the orders would be changed (P=0.002).

DISCUSSION

Hospitals are accountable for safe and effective care of patients with hyperglycemia, which includes prevention of medication‐induced hypoglycemia. We have developed a predictive informatics hypoglycemia risk alert that, when tested in a real‐world situation, significantly reduced the rate of SH in hospitalized patients without increasing severe hyperglycemia. The alert algorithm correctly identified patients who were at high risk for hypoglycemia and allowed caretakers the opportunity to lower that risk. The positive predictive value of the alert was low but acceptable at 9.7%, owing to the overall low rate of hypoglycemia in the patient population.

The alert model tested involved 3 components for success: the automated alert, trained charge nurse responders, and an interaction between the nurse responder and the care provider. HR‐I patients were interviewed and assessed for problems associated with oral intake, dietary habits, medication compliance, and hypoglycemia at home prior to communicating with physicians. The extensive training and proficiency in patient assessment and SBAR communication process required by nurses was paramount in the success of the alert. However, the alert provided a definitive risk assessment that was actionable, versus more global instruction, which has not had the same impact in risk reduction. Based on feedback collected from nurses at the study end, they felt the alert process was within their scope of practice and was not unduly burdensome. They also found that the training in diabetes management and SBAR communication techniques, in addition to the alert system, were useful in protecting patients from medication harm.

Physicians for HR‐C patients missed many opportunities to effectively intervene and thereby reduce the likelihood of an SH event. Our assumption is that the clinicians did not ascertain the risk of SH, which was reflected by the fact that orders were changed in 40.7% of HR‐I patients versus only 20.5% in the HR‐C group. Having alerts go directly to nurses rather than physicians permitted inclusion of additional information, such as caloric intake and testing schedules, so that changes in orders would have greater context, and the importance of mild hypoglycemia would not be overlooked.[16] Glycemic control is challenging for providers in the inpatient setting, as there is little time to test and titrate doses of insulin to achieve control. Tight glycemic control has become the primary focus of diabetes management in the outpatient setting to reduce long‐term risks of microvascular complications.[17, 18] However, establishing glycemic targets in the inpatient setting has been difficult because the risk for hypoglycemia increases with tighter control.[19, 20] Inpatient hypoglycemia has been associated with increased mortality, particularly in critically ill patients.[21, 22] Many factors contribute to hypoglycemia including low creatinine clearance, low body weight, untested insulin doses, errors in insulin administration, unexpected dietary changes, changes in medications affecting BG levels, poor communication during times of patient transfer to different care teams, and poor coordination of BG testing with insulin administration at meal times. A multifaceted approach aimed at improving both clinician and nurse awareness, and providing real‐time risk assessment is clearly required to insure patient safety.[6, 13, 23, 24]

There are significant economic benefits to avoiding SH in the hospital given the adverse outcomes associated with HACs and the extra cost associated with these conditions. In hospitalized patients, hypoglycemia worsens outcomes leading to higher costs due to longer LOS (by 3 days), higher inpatient charges (38.9%), and higher risk of discharge to a skilled nursing facility.[1, 3, 25, 26] Conversely, improved glycemic control can reduce surgical site infections, perioperative morbidity, and hospital LOS.[27] The high prevalence of insulin use among inpatients, many of whom have high‐risk characteristics, creates a milieu for both hyper‐ and hypoglycemia. Other groups have described a drop in hypoglycemia rates related to the use of standardized diabetes order sets and nurse and physician education, but this is the first study that used informatics in a prospective manner to identify patients who are at high risk for developing hypoglycemia and then specifically targeted those patients.[28] The alert process was modeled after a similar alert developed in our institution for identifying medicine patients at risk for sepsis.[29] Given the paucity of data related to inpatient glycemia risk reduction, this study is particularly relevant for improving patient safety.

The major limitation of this study is that it was not randomized at the patient level. Patients were assigned to intervention and control groups based on their occupancy on specific hospital floors to avoid treatment bias. Bias was assessed due to this nonrandom assignment by comparing demographic and clinical factors of HR patients between intervention and control floors, and found significant differences in HbA1c and admitting diagnosis. As the control group had lower HbA1c values than the intervention group, and it is known from the Diabetes Control and Complications Trial and Action to Control Cardiovascular Risk in Diabetes trial that lower HbA1c increases the risk of hypoglycemia, our results may be biased by the level of glucose control on admission.[30, 31] Admitting diagnoses differed significantly between intervention and control patients as did the Charlson Comorbidity Index score; however, the hypoglycemia alert system does not include patient diagnoses or comorbidities, and as such provided equipoise with regard to risk reduction regardless of presenting illness. This study included trained nurses, which may be beyond the scope of every institution and thereby limit the effectiveness of the alert in reducing risk. However, as a result of this study, the alert was expanded to other acute care floors at our hospital as well as other hospitals in the Barnes‐Jewish Hospital system.

In summary, this study showed a 68% decrease in episodes of SH in a high‐risk patient cohort on diabetic medications using a hypoglycemia alert system. The results of this study demonstrate the validity of a systems‐based approach to reduce SH in high‐risk inpatients.

Disclosures

This work was funded by the Barnes‐Jewish Hospital Foundation The authors report no conflicts of interest.

References
  1. Nirantharakumar K, Marshall T, Kennedy A, Narendran P, Hemming K, Coleman JJ. Hypoglycaemia is associated with increased length of stay and mortality in people with diabetes who are hospitalized. Diabet Med. 2012;29:e445e448.
  2. Kagansky N, Levy S, Rimon E, et al. Hypoglycemia as a predictor of mortality in hospitalized elderly patients. Arch Intern Med. 2003;163:18251829.
  3. Turchin A, Matheny ME, Shubina M, Scanlon JV, Greenwood B, Pendergrass ML. Hypoglycemia and clinical outcomes in patients with diabetes hospitalized in the general ward. Diabetes Care. 2009;32:11531157.
  4. Desouza C, Salazar H, Cheong B, Murgo J, Fonseca V. Association of hypoglycemia and cardiac ischemia: a study based on continuous glucose monitoring. Diabetes Care. 2003;26:14851489.
  5. Schwartz AV, Vittinghoff E, Sellmeyer DE, et al. Diabetes‐related complications, glycemic control, and falls in older adults. Diabetes Care. 2008;31:391396.
  6. Deal EN, Liu A, Wise LL, Honick KA, Tobin GS. Inpatient insulin orders: are patients getting what is prescribed? J Hosp Med. 2011;9:526529.
  7. Elliot MB, Schafers SJ, McGill JM, Tobin GS. Prediction and prevention of treatment‐related inpatient hypoglycemia. J Diabetes Sci Technol. 2012;6:302309.
  8. Baggs JG, Schmitt MH. Collaboration between nurses and physicians. Image J Nurs Sch. 1988;20:145149.
  9. Goldberg PA, Bozzo JE, Thomas PG, et al. Glucometrics—assessing the quality of inpatient glucose management. Diabetes Technol Ther. 2005;8:560569.
  10. ACE/ADA Task Force on Inpatient Diabetes. American College of Endocrinology and American Diabetes Association consensus statement on inpatient diabetes and glycemic control. Diabetes Care. 2006;29:19551962.
  11. Moghissi ES, Korytkowski MT, DiNardo M, et al. American Association of Clinical Endocrinologists and American Diabetes Association consensus statement on inpatient glycemic control. Endocr Pract. 2009;15:353369.
  12. Kesten KS. Role‐play using SBAR technique to improve observed communication skills in senior nursing students. J Nurs Educ. 2011;50:7987.
  13. SHM Glycemic Control Task Force. Workbook for improvement: improving glycemic control, preventing hypoglycemia, and optimizing care of the inpatient with hyperglycemia and diabetes. Society of Hospital Medicine website, Glycemic Control Quality Improvement Resource Room. Available at: http://www.hospitalmedicine.org. Accessed on February 12, 2011.
  14. Thomas P, Inzucchi SE. An internet service supporting quality assessment of inpatient glycemic control. J Diabetes Sci and Technol. 2008;2:402408.
  15. Quan H, Li B, Couris C, et al. Updating and validating the Charlson Comorbidity Index and score for risk adjustment in hospital discharge abstracts using data from 6 countries. Am J Epidemiol. 2011;173:676682.
  16. Hawkins K, Donihi AC, Korytkowski MT. Glycemic management in medical and surgical patients in the non‐ICU setting. Curr Diab Rep. 2013;13:96106.
  17. The Diabetes Control and Complications Trial Research Group. The effect of intensive treatment of diabetes on the development and progression of long‐term complications in insulin‐dependent diabetes mellitus. N Engl J Med. 1993;329:977986.
  18. UK Prospective Diabetes Study Group. Intensive blood‐glucose control with sulphonylureas or insulin compared with conventional treatment and risk of complications in patients with type 2 diabetes. Lancet. 1998;352:837853.
  19. Cryer PE, Davis SN, Shamoon H. Hypoglycemia in diabetes. Diabetes Care. 2003;26:19021912.
  20. Cryer PE. Hypoglycemia: still the limiting factor in the glycemic management of diabetes. Endocr Pract. 2008;14:750756.
  21. Finfer S, Liu B, Chittock DR, et al.; for the NICE‐SUGAR Study Investigators. Hypoglycemia and risk of death in critically ill patients. N Engl J Med. 2012;367:11081118.
  22. McCoy RG, Houten HK, Ziegenfuss JY, Shah ND, Wermers RA, Smith SA. Increased mortality of patients with diabetes reporting severe hypoglycemia. Diabetes Care. 2012;35:18971901.
  23. Farrokhi F, Klindukhova O, Chandra P, et al. Risk factors for inpatient hypoglycemia during subcutaneous insulin therapy in non‐critically ill patients with type 2 diabetes. J Diabetes Sci Technol. 2012;6:10221029.
  24. Selig PM, Popek V, Peebles KM. Minimizing hypoglycemia in the wake of a tight glycemic control protocol in hospitalized patients. J Nurs Care Qual. 2010;25:255260.
  25. Lundkvist J, Berne C, Bolinder B, Jonsson L. The economic and quality of life impact of hypoglycemia. Eur J Health Econ. 2005;6:197202.
  26. Curkendall SM, Natoli JL, Alexander CM, Nathanson BH, Haidar T, Dubois RW. Economic and clinical impact of inpatient diabetic hypoglycemia. Endocr Pract. 2009;15:302312.
  27. Kringsley J, Schultz MJ, Spronk PE, et al. Mild hypoglycemia is strongly associated with increased intensive care unit length of stay. Ann Intensive Care. 2011;49:149.
  28. Munoz M, Pronovost P, Dintzis J, et al. Implementing and evaluating a multicomponent inpatient diabetes management program: putting research into practice. Jt Comm J Qual Patient Saf. 2012;38:195206.
  29. Sawyer AM, Deal EN, Labelle AJ, et al. Implementation of a real‐time computerized sepsis alert in nonintensive care unit patients. Crit Care Med. 2011;39:469473.
  30. The Diabetes Control and Complications Trial Research Group. Epidemiology of severe hypoglycemia in the Diabetes Control and Complications Trial. Am J Med. 1991;90:450459.
  31. Miller ME, Bonds DE, Gerstein HC, et al. The effects of baseline characteristics, glycemia treatment approach, and glycated hemoglobin concentration on the risk of severe hypoglycaemia: post hoc epidemiological analysis of the ACCORD study. BMJ. 2010;340:112.
References
  1. Nirantharakumar K, Marshall T, Kennedy A, Narendran P, Hemming K, Coleman JJ. Hypoglycaemia is associated with increased length of stay and mortality in people with diabetes who are hospitalized. Diabet Med. 2012;29:e445e448.
  2. Kagansky N, Levy S, Rimon E, et al. Hypoglycemia as a predictor of mortality in hospitalized elderly patients. Arch Intern Med. 2003;163:18251829.
  3. Turchin A, Matheny ME, Shubina M, Scanlon JV, Greenwood B, Pendergrass ML. Hypoglycemia and clinical outcomes in patients with diabetes hospitalized in the general ward. Diabetes Care. 2009;32:11531157.
  4. Desouza C, Salazar H, Cheong B, Murgo J, Fonseca V. Association of hypoglycemia and cardiac ischemia: a study based on continuous glucose monitoring. Diabetes Care. 2003;26:14851489.
  5. Schwartz AV, Vittinghoff E, Sellmeyer DE, et al. Diabetes‐related complications, glycemic control, and falls in older adults. Diabetes Care. 2008;31:391396.
  6. Deal EN, Liu A, Wise LL, Honick KA, Tobin GS. Inpatient insulin orders: are patients getting what is prescribed? J Hosp Med. 2011;9:526529.
  7. Elliot MB, Schafers SJ, McGill JM, Tobin GS. Prediction and prevention of treatment‐related inpatient hypoglycemia. J Diabetes Sci Technol. 2012;6:302309.
  8. Baggs JG, Schmitt MH. Collaboration between nurses and physicians. Image J Nurs Sch. 1988;20:145149.
  9. Goldberg PA, Bozzo JE, Thomas PG, et al. Glucometrics—assessing the quality of inpatient glucose management. Diabetes Technol Ther. 2005;8:560569.
  10. ACE/ADA Task Force on Inpatient Diabetes. American College of Endocrinology and American Diabetes Association consensus statement on inpatient diabetes and glycemic control. Diabetes Care. 2006;29:19551962.
  11. Moghissi ES, Korytkowski MT, DiNardo M, et al. American Association of Clinical Endocrinologists and American Diabetes Association consensus statement on inpatient glycemic control. Endocr Pract. 2009;15:353369.
  12. Kesten KS. Role‐play using SBAR technique to improve observed communication skills in senior nursing students. J Nurs Educ. 2011;50:7987.
  13. SHM Glycemic Control Task Force. Workbook for improvement: improving glycemic control, preventing hypoglycemia, and optimizing care of the inpatient with hyperglycemia and diabetes. Society of Hospital Medicine website, Glycemic Control Quality Improvement Resource Room. Available at: http://www.hospitalmedicine.org. Accessed on February 12, 2011.
  14. Thomas P, Inzucchi SE. An internet service supporting quality assessment of inpatient glycemic control. J Diabetes Sci and Technol. 2008;2:402408.
  15. Quan H, Li B, Couris C, et al. Updating and validating the Charlson Comorbidity Index and score for risk adjustment in hospital discharge abstracts using data from 6 countries. Am J Epidemiol. 2011;173:676682.
  16. Hawkins K, Donihi AC, Korytkowski MT. Glycemic management in medical and surgical patients in the non‐ICU setting. Curr Diab Rep. 2013;13:96106.
  17. The Diabetes Control and Complications Trial Research Group. The effect of intensive treatment of diabetes on the development and progression of long‐term complications in insulin‐dependent diabetes mellitus. N Engl J Med. 1993;329:977986.
  18. UK Prospective Diabetes Study Group. Intensive blood‐glucose control with sulphonylureas or insulin compared with conventional treatment and risk of complications in patients with type 2 diabetes. Lancet. 1998;352:837853.
  19. Cryer PE, Davis SN, Shamoon H. Hypoglycemia in diabetes. Diabetes Care. 2003;26:19021912.
  20. Cryer PE. Hypoglycemia: still the limiting factor in the glycemic management of diabetes. Endocr Pract. 2008;14:750756.
  21. Finfer S, Liu B, Chittock DR, et al.; for the NICE‐SUGAR Study Investigators. Hypoglycemia and risk of death in critically ill patients. N Engl J Med. 2012;367:11081118.
  22. McCoy RG, Houten HK, Ziegenfuss JY, Shah ND, Wermers RA, Smith SA. Increased mortality of patients with diabetes reporting severe hypoglycemia. Diabetes Care. 2012;35:18971901.
  23. Farrokhi F, Klindukhova O, Chandra P, et al. Risk factors for inpatient hypoglycemia during subcutaneous insulin therapy in non‐critically ill patients with type 2 diabetes. J Diabetes Sci Technol. 2012;6:10221029.
  24. Selig PM, Popek V, Peebles KM. Minimizing hypoglycemia in the wake of a tight glycemic control protocol in hospitalized patients. J Nurs Care Qual. 2010;25:255260.
  25. Lundkvist J, Berne C, Bolinder B, Jonsson L. The economic and quality of life impact of hypoglycemia. Eur J Health Econ. 2005;6:197202.
  26. Curkendall SM, Natoli JL, Alexander CM, Nathanson BH, Haidar T, Dubois RW. Economic and clinical impact of inpatient diabetic hypoglycemia. Endocr Pract. 2009;15:302312.
  27. Kringsley J, Schultz MJ, Spronk PE, et al. Mild hypoglycemia is strongly associated with increased intensive care unit length of stay. Ann Intensive Care. 2011;49:149.
  28. Munoz M, Pronovost P, Dintzis J, et al. Implementing and evaluating a multicomponent inpatient diabetes management program: putting research into practice. Jt Comm J Qual Patient Saf. 2012;38:195206.
  29. Sawyer AM, Deal EN, Labelle AJ, et al. Implementation of a real‐time computerized sepsis alert in nonintensive care unit patients. Crit Care Med. 2011;39:469473.
  30. The Diabetes Control and Complications Trial Research Group. Epidemiology of severe hypoglycemia in the Diabetes Control and Complications Trial. Am J Med. 1991;90:450459.
  31. Miller ME, Bonds DE, Gerstein HC, et al. The effects of baseline characteristics, glycemia treatment approach, and glycated hemoglobin concentration on the risk of severe hypoglycaemia: post hoc epidemiological analysis of the ACCORD study. BMJ. 2010;340:112.
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Address for correspondence and reprint requests: Garry S. Tobin, MD, Campus Box 8127, Washington University School of Medicine, 660 South Euclid Avenue, St. Louis, MO 63110; Telephone: 314‐362‐4417; Fax: 314‐362‐7641; E‐mail: [email protected]
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Clinical Deterioration Alerts

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A randomized trial of real‐time automated clinical deterioration alerts sent to a rapid response team

Patients deemed suitable for care on a general hospital unit are not expected to deteriorate; however, triage systems are not perfect, and some patients on general nursing units do develop critical illness during their hospitalization. Fortunately, there is mounting evidence that deteriorating patients exhibit measurable pathologic changes that could possibly be used to identify them prior to significant adverse outcomes, such as cardiac arrest.[1, 2, 3] Given the evidence that unplanned intensive care unit (ICU) transfers of patients on general units result in worse outcomes than more controlled ICU admissions,[1, 4, 5, 6] it is logical to assume that earlier identification of a deteriorating patient could provide a window of opportunity to prevent adverse outcomes.

The most commonly proposed systematic solution to the problem of identifying and stabilizing deteriorating patients on general hospital units includes some combination of an early warning system (EWS) to detect the deterioration and a rapid response team (RRT) to deal with it.[7, 8, 9, 10] We previously demonstrated that a relatively simple hospital‐specific method for generating EWS alerts derived from the electronic medical record (EMR) database is capable of predicting clinical deterioration and the need for ICU transfer, as well as hospital mortality, in non‐ICU patients admitted to general inpatient medicine units.[11, 12, 13, 14] However, our data also showed that simply providing the EWS alerts to these nursing units did not result in any demonstrable improvement in patient outcomes.[14] Therefore, we set out to determine whether linking real‐time EWS alerts to an intervention and notification of the RRT for patient evaluation could improve the outcomes of patients cared for on general inpatient units.

METHODS

Study Location

The study was conducted on 8 adult inpatient medicine units of Barnes‐Jewish Hospital, a 1250‐bed academic medical center in St. Louis, MO (January 15, 2013May 9, 2013). Patient care on the inpatient medicine units is delivered by either attending hospitalist physicians or dedicated housestaff physicians under the supervision of an attending physician. Continuous electronic vital sign monitoring is not provided on these units. The study was approved by the Washington University School of Medicine Human Studies Committee, and informed consent was waived. This was a nonblinded study (ClinicalTrials.gov Identifier: NCT01741480).

Patients and Procedures

Patients admitted to the 8 medicine units received usual care during the study except as noted below. Manually obtained vital signs, laboratory data, and pharmacy data inputted in real time into the EMR were continuously assessed. The EWS searched for the 36 input variables previously described[11, 14] from the EMR for all patients admitted to the 8 medicine units 24 hours per day and 7 days a week. Values for every continuous parameter were scaled so that all measurements lay in the interval (0, 1) and were normalized by the minimum and maximum of the parameter as previously described.[14] To capture the temporal effects in our data, we retained a sliding window of all the collected data points within the last 24 hours. We then subdivided these data into a series of 6 sequential buckets of 4 hours each. We excluded the 2 hours of data prior to ICU transfer in building the model (so the data were 26 hours to 2 hours prior to ICU transfer for ICU transfer patients, and the first 24 hours of admission for everyone else). Eligible patients were selected for study entry when they triggered an alert for clinical deterioration as determined by the EWS.[11, 14]

The EWS alert was implemented in an internally developed, Java‐based clinical decision support rules engine, which identified when new data relevant to the model were available in a real‐time central data repository. In a clinical application, it is important to capture unusual changes in vital‐sign data over time. Such changes may precede clinical deterioration by hours, providing a chance to intervene if detected early enough. In addition, not all readings in time‐series data should be treated equally; the value of some kinds of data may change depending on their age. For example, a patient's condition may be better reflected by a blood‐oxygenation reading collected 1 hour ago than a reading collected 12 hours ago. This is the rationale for our use of a sliding window of all collected data points within the last 24 hours performed on a real‐time basis to determine the alert status of the patient.[11, 14]

We applied various threshold cut points to convert the EWS alert predictions into binary values and compared the results against the actual ICU transfer outcome.[14] A threshold of 0.9760 for specificity was chosen to achieve a sensitivity of approximately 40%. These operating characteristics were chosen in turn to generate a manageable number of alerts per hospital nursing unit per day (estimated at 12 per nursing unit per day). At this cut point, the C statistic was 0.8834, with an overall accuracy of 0.9292. In other words, our EWS alert system is calibrated so that for every 1000 patient discharges per year from these 8 hospital units, there would be 75 patients generating an alert, of which 30 patients would be expected to have the study outcome (ie, clinical deterioration requiring ICU transfer).

Once patients on the study units were identified as at risk for clinical deterioration by the EWS, they were assigned by a computerized random number generator to the intervention group or the control group. The control group was managed according to the usual care provided on the medicine units. The EWS alerts generated for the control patients were electronically stored, but these alerts were not sent to the RRT nurse, instead they were hidden from all clinical staff. The intervention group had their EWS alerts sent real time to the nursing member of the hospital's RRT. The RRT is composed of a registered nurse, a second‐ or third‐year internal medicine resident, and a respiratory therapist. The RRT was introduced in 2009 for the study units involved in this investigation. For 2009, 2010, and 2011 the RRT nurse was pulled from the staff of 1 of the hospital's ICUs in a rotating manner to respond to calls to the RRT as they occurred. Starting in 2012, the RRT nurse was established as a dedicated position without other clinical responsibilities. The RRT nurse carries a hospital‐issued mobile phone, to which the automated alert messages were sent real time, and was instructed to respond to all EWS alerts within 20 minutes of their receipt.

The RRT nurse would initially evaluate the alerted intervention patients using the Modified Early Warning Score[15, 16] and make further clinical and triage decisions based on those criteria and discussions with the RRT physician or the patient's treating physicians. The RRT focused their interventions using an internally developed tool called the Four Ds (discuss goals of care, drugs needing to be administered, diagnostics needing to be performed, and damage control with the use of oxygen, intravenous fluids, ventilation, and blood products). Patients evaluated by the RRT could have their current level of care maintained, have the frequency of vital sign monitoring increased, be transferred to an ICU, or have a code blue called for emergent resuscitation. The RRT reviewed goals of care for all patients to determine the appropriateness of interventions, especially for patients near the end of life who did not desire intensive care interventions. Nursing staff on the hospital units could also make calls to the RRT for patient evaluation at any time based on their clinical assessments performed during routine nursing rounds.

The primary efficacy outcome was the need for ICU transfer. Secondary outcome measures were hospital mortality and hospital length of stay. Pertinent demographic, laboratory, and clinical data were gathered prospectively including age, gender, race, underlying comorbidities, and severity of illness assessed by the Charlson comorbidity score and Elixhauser comorbidities.[17, 18]

Statistical Analysis

We required a sample size of 514 patients (257 per group) to achieve 80% power at a 5% significance level, based on the superiority design, a baseline event rate for ICU transfer of 20.0%, and an absolute reduction of 8.0% (PS Power and Sample Size Calculations, version 3.0, Vanderbilt Biostatistics, Nashville, TN). Continuous variables were reported as means with standard deviations or medians with 25th and 75th percentiles according to their distribution. The Student t test was used when comparing normally distributed data, and the Mann‐Whitney U test was employed to analyze non‐normally distributed data (eg, hospital length of stay). Categorical data were expressed as frequency distributions, and the [2] test was used to determine if differences existed between groups. A P value <0.05 was regarded as statistically significant. An interim analysis was planned for the data safety monitoring board to evaluate patient safety after 50% of the patients were recruited. The primary analysis was by intention to treat. Analyses were performed using SPSS version 11.0 for Windows (SPSS, Inc., Chicago, IL).

Data Safety Monitoring Board

An independent data safety and monitoring board was convened to monitor the study and to review and approve protocol amendments by the steering committee.

RESULTS

Between January 15, 2013 and May 9, 2013, there were 4731 consecutive patients admitted to the 8 inpatient units and electronically screened as the base population for this investigation. Five hundred seventy‐one (12.1%) patients triggered an alert and were enrolled into the study (Figure 1). There were 286 patients assigned to the intervention group and 285 assigned to the control group. No patients were lost to follow‐up. Demographics, reason for hospital admission, and comorbidities of the 2 groups were similar (Table 1). The number of patients having a separate RRT call by the primary nursing team on the hospital units within 24 hours of generating an alert was greater for the intervention group but did not reach statistical significance (19.9% vs 16.5%; odds ratio: 1.260; 95% confidence interval [CI]: 0.8231.931). Table 2 provides the new diagnostic and therapeutic interventions initiated within 24 hours after a EWS alert was generated. Patients in the intervention group were significantly more likely to have their primary care team physician notified by an RRT nurse regarding medical condition issues and to have oximetry and telemetry started, whereas control patients were significantly more likely to have new antibiotic orders written within 24 hours of generating an alert.

Figure 1
Study flow diagram. Abbreviations: ICU, intensive care unit.
Baseline Data
VariableIntervention Group, n=286Control Group, n=285P Value
Age, y63.7 16.063.1 15.40.495
Gender, n (%)   
Male132 (46.2)140 (49.1)0.503
Female154 (53.8)145 (50.9) 
Race, n (%)   
Caucasian155 (54.2)154 (54.0)0.417
African American105 (36.7)113 (39.6) 
Other26 (9.1)18 (6.3) 
Reason for hospital admission   
Cardiac12 (4.2)15 (5.3)0.548
Pulmonary64 (22.4)72 (25.3)0.418
Underlying malignancy6 (2.1)3 (1.1)0.504
Renal disease31 (10.8)22 (7.7)0.248
Thromboembolism4 (1.4)5 (1.8)0.752
Infection55 (19.2)50 (17.5)0.603
Neurologic disease33 (11.5)22 (7.7)0.122
Intra‐abdominal disease41 (14.3)47 (16.5)0.476
Hematologic condition4 (1.4)5 (1.8)0.752
Endocrine disorder12 (4.2)6 (2.1)0.153
Source of hospital admission   
Emergency department201 (70.3)203 (71.2)0.200
Direct admission36 (12.6)46 (16.1) 
Hospital transfer49 (17.1)36 (12.6) 
Charlson score6.7 3.66.6 3.20.879
Elixhauser comorbidities score7.4 3.57.5 3.40.839
Diagnostic and Therapeutic Interventions Initiated Within 24 Hours of Generating an Alert
VariableIntervention Group, n=286Control Group, n=285P Value
  • NOTE: Abbreviations: RRT, rapid response team.

Medications, n (%)   
Antibiotics92 (32.2)121 (42.5)0.011
Antiarrhythmics48 (16.8)44 (15.4)0.662
Anticoagulants83 (29.0)97 (34.0)0.197
Diuretics/antihypertensives71 (24.8)55 (19.3)0.111
Bronchodilators78 (27.3)73 (25.6)0.653
Anticonvulsives26 (9.1)27 (9.5)0.875
Sedatives/narcotics0 (0.0)1 (0.4)0.499
Respiratory support, n (%)   
Noninvasive ventilation17 (6.0)9 (3.1)0.106
Escalated oxygen support12 (4.2)7 (2.5)0.247
Enhanced vital signs, n (%)50 (17.5)47 (16.5)0.752
Maintenance intravenous fluids, n (%)48 (16.8)41 (14.4)0.430
Vasopressors, n (%)57 (19.9)61 (21.4)0.664
Bolus intravenous fluids, n (%)7 (2.4)14 (4.9)0.118
Telemetry, n (%)198 (69.2)176 (61.8)0.052
Oximetry, n (%)20 (7.0)6 (2.1)0.005
New intravenous access, n (%)26 (9.1)35 (12.3)0.217
Primary care team physician called by RRT nurse, n (%)82 (28.7)56 (19.6)0.012

Fifty‐one patients (17.8%) randomly assigned to the intervention group required ICU transfer compared with 52 of 285 patients (18.2%) in the control group (odds ratio: 0.972; 95% CI: 0.6351.490; P=0.898) (Table 3). Twenty‐one patients (7.3%) randomly assigned to the intervention group expired during their hospitalization compared with 22 of 285 patients (7.7%) in the control group (odds ratio: 0.947; 95%CI: 0.5091.764; P=0.865). Hospital length of stay was 8.49.5 days (median, 4.5 days; interquartile range, 2.311.4 days) for patients randomized to the intervention group and 9.411.1 days (median, 5.3 days; interquartile range, 3.211.2 days) for patients randomized to the control group (P=0.038). The ICU length of stay was 4.86.6 days (median, 2.9 days; interquartile range, 1.76.5 days) for patients randomized to the intervention group and 5.86.4 days (median, 2.9 days; interquartile range, 1.57.4) for patients randomized to the control group (P=0.812).The number of patients requiring transfer to a nursing home or long‐term acute care hospital was similar for patients in the intervention and control groups (26.9% vs 26.3%; odds ratio: 1.032; 95% CI: 0.7121.495; P=0.870). Similarly, the number of patients requiring hospital readmission before 30 days and 180 days, respectively, was similar for the 2 treatment groups (Table 3). For the combined study population, the EWS alerts were triggered 94138 hours (median, 27 hours; interquartile range, 7132 hours) prior to ICU transfer and 250204 hours (median200 hours; interquartile range, 54347 hours) prior to hospital mortality. The number of RRT calls for the 8 medicine units studied progressively increased from the start of the RRT program in 2009 through 2013 (121 in 2009, 194 in 2010, 298 in 2011, 415 in 2012, 415 in 2013; P<0.001 for the trend).

Outcomes
OutcomeIntervention Group, n=286Control Group, n=285P Value
  • NOTE: Abbreviations: ICU, intensive care unit; LTAC, long‐term acute care. *Values expressed as meanstandard deviation, median [interquartile range].

ICU transfer, n (%)51 (17.8)52 (18.2)0.898
All‐cause hospital mortality, n (%)21 (7.3)22 (7.7)0.865
Transfer to nursing home or LTAC, n (%)77 (26.9)75 (26.3)0.870
30‐day readmission, n (%)53 (18.5)62 (21.8)0.337
180‐day readmission, n (%)124 (43.4)117 (41.1)0.577
Hospital length of stay, d*8.49.5, 4.5 [2.311.4]9.411.1, 5.3 [3.211.2]0.038
ICU length of stay, d*4.86.6, 2.9 [1.76.5]5.86.4, 2.9 [1.57.4]0.812

DISCUSSION

We demonstrated that a real‐time EWS alert sent to a RRT nurse was associated with a modest reduction in hospital length of stay, but similar rates of hospital mortality, ICU transfer, and subsequent need for placement in a long‐term care setting compared with usual care. We also found the number of RRT calls to have increased progressively from 2009 to the present on the study units examined.

Unplanned ICU transfers occurring as early as within 8 hours of hospitalization are relatively common and associated with increased mortality.[6] Bapoje et al. evaluated a total of 152 patients over 1 year who had unplanned ICU transfers.[19] The most common reason was worsening of the problem for which the patient was admitted (48%). Other investigators have also attempted to identify predictors for clinical deterioration resulting in unplanned ICU transfer that could be employed in an EWS.[20, 21] Organizations like the Institute for Healthcare Improvement have called for the development and routine implementation of EWSs to direct the activities of RRTs and improve outcomes.[22] However, a recent systematic review found that much of the evidence in support of EWSs and emergency response teams is of poor quality and lacking prospective randomized trials.[23]

Our earlier experience demonstrated that simply providing an alert to nursing units did not result in any demonstrable improvements in the outcomes of high‐risk patients identified by our EWS.[14] Previous investigations have also had difficulty in demonstrating consistent outcome improvements with the use of EWSs and RRTs.[24, 25, 26, 27, 28, 29, 30, 31, 32] As a result of mandates from quality improvement organizations, most US hospitals currently employ RRTs for emergent mobilization of resources when a clinically deteriorating patient is identified on a hospital ward.[33, 34] Linking RRT actions with a validated real‐time alert may represent a way of improving the overall effectiveness of such teams for monitoring general hospital units, short of having all hospitalized patients in units staffed and monitored to provide higher levels of supervision (eg, ICUs, step‐down units).[9, 35]

An alternative approach to preventing patient deterioration is to provide closer overall monitoring. This has been accomplished by employing nursing personnel to increase monitoring, or with the use of automated monitoring equipment. Bellomo et al. showed that the deployment of electronic automated vital sign monitors on general hospital units was associated with improved utilization of RRTs, increased patient survival, and decreased time for vital sign measurement and recording.[36] Laurens and Dwyer found that implementation of medical emergency teams (METs) to respond to predefined MET activation criteria as observed by hospital staff resulted in reduced hospital mortality and reduced need for ICU transfer.[37] However, other investigators have observed that imperfect implementation of nursing‐performed observational monitoring resulted in no demonstrable benefit, illustrating the limitations of this approach.[38] Our findings suggest that nursing care of patients on general hospital units may be enhanced with the use of an EWS alert sent to the RRT. This is supported by the observation that communications between the RRT and the primary care teams was greater as was the use of telemetry and oximetry in the intervention arm. Moreover, there appears to have been a learning effect for the nursing staff that occurred on our study units, as evidenced by the increased number of RRT calls that occurred between 2009 and 2013. This change in nursing practices on these units certainly made it more difficult for us to observe outcome differences in our current study with the prescribed intervention, reinforcing the notion that evaluating an already established practice is a difficult proposition.[39]

Our study has several important limitations. First, the EWS alert was developed and validated at Barnes‐Jewish Hospital.[11, 12, 13, 14] We cannot say whether this alert will perform similarly in another hospital. Second, the EWS alert only contains data from medical patients. Development and validation of EWS alerts for other hospitalized populations, including surgical and pediatric patients, are needed to make such systems more generalizable. Third, the primary clinical outcome employed for this trial was problematic. Transfer to an ICU may not be an optimal outcome variable, as it may be desirable to transfer alerted patients to an ICU, which can be perceived to represent a soft landing for such patients once an alert has been generated. A better measure could be 30‐day all‐cause mortality, which would not be subject to clinician biases. Finally, we could not specifically identify explanations for the greater use of antibiotics in the control group despite similar rates of infection for both study arms. Future studies should closely evaluate the ability of EWS alerts to alter specific therapies (eg, reduce antibiotic utilization).

In summary, we have demonstrated that an EWS alert linked to a RRT likely contributed to a modest reduction in hospital length of stay, but no reductions in hospital mortality and ICU transfer. These findings suggest that inpatient deterioration on general hospital units can be identified and linked to a specific intervention. Continued efforts are needed to identify and implement systems that will not only accurately identify high‐risk patients on general hospital units but also intervene to improve their outcomes. We are moving forward with the development of a 2‐tiered EWS utilizing both EMR data and real‐time streamed vital sign data, to determine if we can further improve the prediction of clinical deterioration and potentially intervene in a more clinically meaningful manner.

Acknowledgements

The authors thank Ann Doyle, BSN, Lisa Mayfield, BSN, and Darain Mitchell for their assistance in carrying out this research protocol; and William Shannon, PhD, from the Division of General Medical Sciences at Washington University, for statistical support.

Disclosures: This study was funded in part by the Barnes‐Jewish Hospital Foundation, the Chest Foundation of the American College of Chest Physicians, and by grant number UL1 RR024992 from the National Center for Research Resources (NCRR), a component of the National Institutes of Health (NIH), and NIH Roadmap for Medical Research. Its contents are solely the responsibility of the authors and do not necessarily represent the official view of the NCRR or NIH. The steering committee was responsible for the study design, execution, analysis, and content of the article. The Barnes‐Jewish Hospital Foundation, the American College of Chest Physicians, and the Chest Foundation were not involved in the design, conduct, or analysis of the trial. The authors report no conflicts of interest. Marin Kollef, Yixin Chen, Kevin Heard, Gina LaRossa, Chenyang Lu, Nathan Martin, Nelda Martin, Scott Micek, and Thomas Bailey have all made substantial contributions to conception and design, or acquisition of data, or analysis and interpretation of data; have drafted the submitted article or revised it critically for important intellectual content; have provided final approval of the version to be published; and have agreed to be accountable for all aspects of the work in ensuring that questions related to the accuracy or integrity of any part of the work are appropriately investigated and resolved.

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Patients deemed suitable for care on a general hospital unit are not expected to deteriorate; however, triage systems are not perfect, and some patients on general nursing units do develop critical illness during their hospitalization. Fortunately, there is mounting evidence that deteriorating patients exhibit measurable pathologic changes that could possibly be used to identify them prior to significant adverse outcomes, such as cardiac arrest.[1, 2, 3] Given the evidence that unplanned intensive care unit (ICU) transfers of patients on general units result in worse outcomes than more controlled ICU admissions,[1, 4, 5, 6] it is logical to assume that earlier identification of a deteriorating patient could provide a window of opportunity to prevent adverse outcomes.

The most commonly proposed systematic solution to the problem of identifying and stabilizing deteriorating patients on general hospital units includes some combination of an early warning system (EWS) to detect the deterioration and a rapid response team (RRT) to deal with it.[7, 8, 9, 10] We previously demonstrated that a relatively simple hospital‐specific method for generating EWS alerts derived from the electronic medical record (EMR) database is capable of predicting clinical deterioration and the need for ICU transfer, as well as hospital mortality, in non‐ICU patients admitted to general inpatient medicine units.[11, 12, 13, 14] However, our data also showed that simply providing the EWS alerts to these nursing units did not result in any demonstrable improvement in patient outcomes.[14] Therefore, we set out to determine whether linking real‐time EWS alerts to an intervention and notification of the RRT for patient evaluation could improve the outcomes of patients cared for on general inpatient units.

METHODS

Study Location

The study was conducted on 8 adult inpatient medicine units of Barnes‐Jewish Hospital, a 1250‐bed academic medical center in St. Louis, MO (January 15, 2013May 9, 2013). Patient care on the inpatient medicine units is delivered by either attending hospitalist physicians or dedicated housestaff physicians under the supervision of an attending physician. Continuous electronic vital sign monitoring is not provided on these units. The study was approved by the Washington University School of Medicine Human Studies Committee, and informed consent was waived. This was a nonblinded study (ClinicalTrials.gov Identifier: NCT01741480).

Patients and Procedures

Patients admitted to the 8 medicine units received usual care during the study except as noted below. Manually obtained vital signs, laboratory data, and pharmacy data inputted in real time into the EMR were continuously assessed. The EWS searched for the 36 input variables previously described[11, 14] from the EMR for all patients admitted to the 8 medicine units 24 hours per day and 7 days a week. Values for every continuous parameter were scaled so that all measurements lay in the interval (0, 1) and were normalized by the minimum and maximum of the parameter as previously described.[14] To capture the temporal effects in our data, we retained a sliding window of all the collected data points within the last 24 hours. We then subdivided these data into a series of 6 sequential buckets of 4 hours each. We excluded the 2 hours of data prior to ICU transfer in building the model (so the data were 26 hours to 2 hours prior to ICU transfer for ICU transfer patients, and the first 24 hours of admission for everyone else). Eligible patients were selected for study entry when they triggered an alert for clinical deterioration as determined by the EWS.[11, 14]

The EWS alert was implemented in an internally developed, Java‐based clinical decision support rules engine, which identified when new data relevant to the model were available in a real‐time central data repository. In a clinical application, it is important to capture unusual changes in vital‐sign data over time. Such changes may precede clinical deterioration by hours, providing a chance to intervene if detected early enough. In addition, not all readings in time‐series data should be treated equally; the value of some kinds of data may change depending on their age. For example, a patient's condition may be better reflected by a blood‐oxygenation reading collected 1 hour ago than a reading collected 12 hours ago. This is the rationale for our use of a sliding window of all collected data points within the last 24 hours performed on a real‐time basis to determine the alert status of the patient.[11, 14]

We applied various threshold cut points to convert the EWS alert predictions into binary values and compared the results against the actual ICU transfer outcome.[14] A threshold of 0.9760 for specificity was chosen to achieve a sensitivity of approximately 40%. These operating characteristics were chosen in turn to generate a manageable number of alerts per hospital nursing unit per day (estimated at 12 per nursing unit per day). At this cut point, the C statistic was 0.8834, with an overall accuracy of 0.9292. In other words, our EWS alert system is calibrated so that for every 1000 patient discharges per year from these 8 hospital units, there would be 75 patients generating an alert, of which 30 patients would be expected to have the study outcome (ie, clinical deterioration requiring ICU transfer).

Once patients on the study units were identified as at risk for clinical deterioration by the EWS, they were assigned by a computerized random number generator to the intervention group or the control group. The control group was managed according to the usual care provided on the medicine units. The EWS alerts generated for the control patients were electronically stored, but these alerts were not sent to the RRT nurse, instead they were hidden from all clinical staff. The intervention group had their EWS alerts sent real time to the nursing member of the hospital's RRT. The RRT is composed of a registered nurse, a second‐ or third‐year internal medicine resident, and a respiratory therapist. The RRT was introduced in 2009 for the study units involved in this investigation. For 2009, 2010, and 2011 the RRT nurse was pulled from the staff of 1 of the hospital's ICUs in a rotating manner to respond to calls to the RRT as they occurred. Starting in 2012, the RRT nurse was established as a dedicated position without other clinical responsibilities. The RRT nurse carries a hospital‐issued mobile phone, to which the automated alert messages were sent real time, and was instructed to respond to all EWS alerts within 20 minutes of their receipt.

The RRT nurse would initially evaluate the alerted intervention patients using the Modified Early Warning Score[15, 16] and make further clinical and triage decisions based on those criteria and discussions with the RRT physician or the patient's treating physicians. The RRT focused their interventions using an internally developed tool called the Four Ds (discuss goals of care, drugs needing to be administered, diagnostics needing to be performed, and damage control with the use of oxygen, intravenous fluids, ventilation, and blood products). Patients evaluated by the RRT could have their current level of care maintained, have the frequency of vital sign monitoring increased, be transferred to an ICU, or have a code blue called for emergent resuscitation. The RRT reviewed goals of care for all patients to determine the appropriateness of interventions, especially for patients near the end of life who did not desire intensive care interventions. Nursing staff on the hospital units could also make calls to the RRT for patient evaluation at any time based on their clinical assessments performed during routine nursing rounds.

The primary efficacy outcome was the need for ICU transfer. Secondary outcome measures were hospital mortality and hospital length of stay. Pertinent demographic, laboratory, and clinical data were gathered prospectively including age, gender, race, underlying comorbidities, and severity of illness assessed by the Charlson comorbidity score and Elixhauser comorbidities.[17, 18]

Statistical Analysis

We required a sample size of 514 patients (257 per group) to achieve 80% power at a 5% significance level, based on the superiority design, a baseline event rate for ICU transfer of 20.0%, and an absolute reduction of 8.0% (PS Power and Sample Size Calculations, version 3.0, Vanderbilt Biostatistics, Nashville, TN). Continuous variables were reported as means with standard deviations or medians with 25th and 75th percentiles according to their distribution. The Student t test was used when comparing normally distributed data, and the Mann‐Whitney U test was employed to analyze non‐normally distributed data (eg, hospital length of stay). Categorical data were expressed as frequency distributions, and the [2] test was used to determine if differences existed between groups. A P value <0.05 was regarded as statistically significant. An interim analysis was planned for the data safety monitoring board to evaluate patient safety after 50% of the patients were recruited. The primary analysis was by intention to treat. Analyses were performed using SPSS version 11.0 for Windows (SPSS, Inc., Chicago, IL).

Data Safety Monitoring Board

An independent data safety and monitoring board was convened to monitor the study and to review and approve protocol amendments by the steering committee.

RESULTS

Between January 15, 2013 and May 9, 2013, there were 4731 consecutive patients admitted to the 8 inpatient units and electronically screened as the base population for this investigation. Five hundred seventy‐one (12.1%) patients triggered an alert and were enrolled into the study (Figure 1). There were 286 patients assigned to the intervention group and 285 assigned to the control group. No patients were lost to follow‐up. Demographics, reason for hospital admission, and comorbidities of the 2 groups were similar (Table 1). The number of patients having a separate RRT call by the primary nursing team on the hospital units within 24 hours of generating an alert was greater for the intervention group but did not reach statistical significance (19.9% vs 16.5%; odds ratio: 1.260; 95% confidence interval [CI]: 0.8231.931). Table 2 provides the new diagnostic and therapeutic interventions initiated within 24 hours after a EWS alert was generated. Patients in the intervention group were significantly more likely to have their primary care team physician notified by an RRT nurse regarding medical condition issues and to have oximetry and telemetry started, whereas control patients were significantly more likely to have new antibiotic orders written within 24 hours of generating an alert.

Figure 1
Study flow diagram. Abbreviations: ICU, intensive care unit.
Baseline Data
VariableIntervention Group, n=286Control Group, n=285P Value
Age, y63.7 16.063.1 15.40.495
Gender, n (%)   
Male132 (46.2)140 (49.1)0.503
Female154 (53.8)145 (50.9) 
Race, n (%)   
Caucasian155 (54.2)154 (54.0)0.417
African American105 (36.7)113 (39.6) 
Other26 (9.1)18 (6.3) 
Reason for hospital admission   
Cardiac12 (4.2)15 (5.3)0.548
Pulmonary64 (22.4)72 (25.3)0.418
Underlying malignancy6 (2.1)3 (1.1)0.504
Renal disease31 (10.8)22 (7.7)0.248
Thromboembolism4 (1.4)5 (1.8)0.752
Infection55 (19.2)50 (17.5)0.603
Neurologic disease33 (11.5)22 (7.7)0.122
Intra‐abdominal disease41 (14.3)47 (16.5)0.476
Hematologic condition4 (1.4)5 (1.8)0.752
Endocrine disorder12 (4.2)6 (2.1)0.153
Source of hospital admission   
Emergency department201 (70.3)203 (71.2)0.200
Direct admission36 (12.6)46 (16.1) 
Hospital transfer49 (17.1)36 (12.6) 
Charlson score6.7 3.66.6 3.20.879
Elixhauser comorbidities score7.4 3.57.5 3.40.839
Diagnostic and Therapeutic Interventions Initiated Within 24 Hours of Generating an Alert
VariableIntervention Group, n=286Control Group, n=285P Value
  • NOTE: Abbreviations: RRT, rapid response team.

Medications, n (%)   
Antibiotics92 (32.2)121 (42.5)0.011
Antiarrhythmics48 (16.8)44 (15.4)0.662
Anticoagulants83 (29.0)97 (34.0)0.197
Diuretics/antihypertensives71 (24.8)55 (19.3)0.111
Bronchodilators78 (27.3)73 (25.6)0.653
Anticonvulsives26 (9.1)27 (9.5)0.875
Sedatives/narcotics0 (0.0)1 (0.4)0.499
Respiratory support, n (%)   
Noninvasive ventilation17 (6.0)9 (3.1)0.106
Escalated oxygen support12 (4.2)7 (2.5)0.247
Enhanced vital signs, n (%)50 (17.5)47 (16.5)0.752
Maintenance intravenous fluids, n (%)48 (16.8)41 (14.4)0.430
Vasopressors, n (%)57 (19.9)61 (21.4)0.664
Bolus intravenous fluids, n (%)7 (2.4)14 (4.9)0.118
Telemetry, n (%)198 (69.2)176 (61.8)0.052
Oximetry, n (%)20 (7.0)6 (2.1)0.005
New intravenous access, n (%)26 (9.1)35 (12.3)0.217
Primary care team physician called by RRT nurse, n (%)82 (28.7)56 (19.6)0.012

Fifty‐one patients (17.8%) randomly assigned to the intervention group required ICU transfer compared with 52 of 285 patients (18.2%) in the control group (odds ratio: 0.972; 95% CI: 0.6351.490; P=0.898) (Table 3). Twenty‐one patients (7.3%) randomly assigned to the intervention group expired during their hospitalization compared with 22 of 285 patients (7.7%) in the control group (odds ratio: 0.947; 95%CI: 0.5091.764; P=0.865). Hospital length of stay was 8.49.5 days (median, 4.5 days; interquartile range, 2.311.4 days) for patients randomized to the intervention group and 9.411.1 days (median, 5.3 days; interquartile range, 3.211.2 days) for patients randomized to the control group (P=0.038). The ICU length of stay was 4.86.6 days (median, 2.9 days; interquartile range, 1.76.5 days) for patients randomized to the intervention group and 5.86.4 days (median, 2.9 days; interquartile range, 1.57.4) for patients randomized to the control group (P=0.812).The number of patients requiring transfer to a nursing home or long‐term acute care hospital was similar for patients in the intervention and control groups (26.9% vs 26.3%; odds ratio: 1.032; 95% CI: 0.7121.495; P=0.870). Similarly, the number of patients requiring hospital readmission before 30 days and 180 days, respectively, was similar for the 2 treatment groups (Table 3). For the combined study population, the EWS alerts were triggered 94138 hours (median, 27 hours; interquartile range, 7132 hours) prior to ICU transfer and 250204 hours (median200 hours; interquartile range, 54347 hours) prior to hospital mortality. The number of RRT calls for the 8 medicine units studied progressively increased from the start of the RRT program in 2009 through 2013 (121 in 2009, 194 in 2010, 298 in 2011, 415 in 2012, 415 in 2013; P<0.001 for the trend).

Outcomes
OutcomeIntervention Group, n=286Control Group, n=285P Value
  • NOTE: Abbreviations: ICU, intensive care unit; LTAC, long‐term acute care. *Values expressed as meanstandard deviation, median [interquartile range].

ICU transfer, n (%)51 (17.8)52 (18.2)0.898
All‐cause hospital mortality, n (%)21 (7.3)22 (7.7)0.865
Transfer to nursing home or LTAC, n (%)77 (26.9)75 (26.3)0.870
30‐day readmission, n (%)53 (18.5)62 (21.8)0.337
180‐day readmission, n (%)124 (43.4)117 (41.1)0.577
Hospital length of stay, d*8.49.5, 4.5 [2.311.4]9.411.1, 5.3 [3.211.2]0.038
ICU length of stay, d*4.86.6, 2.9 [1.76.5]5.86.4, 2.9 [1.57.4]0.812

DISCUSSION

We demonstrated that a real‐time EWS alert sent to a RRT nurse was associated with a modest reduction in hospital length of stay, but similar rates of hospital mortality, ICU transfer, and subsequent need for placement in a long‐term care setting compared with usual care. We also found the number of RRT calls to have increased progressively from 2009 to the present on the study units examined.

Unplanned ICU transfers occurring as early as within 8 hours of hospitalization are relatively common and associated with increased mortality.[6] Bapoje et al. evaluated a total of 152 patients over 1 year who had unplanned ICU transfers.[19] The most common reason was worsening of the problem for which the patient was admitted (48%). Other investigators have also attempted to identify predictors for clinical deterioration resulting in unplanned ICU transfer that could be employed in an EWS.[20, 21] Organizations like the Institute for Healthcare Improvement have called for the development and routine implementation of EWSs to direct the activities of RRTs and improve outcomes.[22] However, a recent systematic review found that much of the evidence in support of EWSs and emergency response teams is of poor quality and lacking prospective randomized trials.[23]

Our earlier experience demonstrated that simply providing an alert to nursing units did not result in any demonstrable improvements in the outcomes of high‐risk patients identified by our EWS.[14] Previous investigations have also had difficulty in demonstrating consistent outcome improvements with the use of EWSs and RRTs.[24, 25, 26, 27, 28, 29, 30, 31, 32] As a result of mandates from quality improvement organizations, most US hospitals currently employ RRTs for emergent mobilization of resources when a clinically deteriorating patient is identified on a hospital ward.[33, 34] Linking RRT actions with a validated real‐time alert may represent a way of improving the overall effectiveness of such teams for monitoring general hospital units, short of having all hospitalized patients in units staffed and monitored to provide higher levels of supervision (eg, ICUs, step‐down units).[9, 35]

An alternative approach to preventing patient deterioration is to provide closer overall monitoring. This has been accomplished by employing nursing personnel to increase monitoring, or with the use of automated monitoring equipment. Bellomo et al. showed that the deployment of electronic automated vital sign monitors on general hospital units was associated with improved utilization of RRTs, increased patient survival, and decreased time for vital sign measurement and recording.[36] Laurens and Dwyer found that implementation of medical emergency teams (METs) to respond to predefined MET activation criteria as observed by hospital staff resulted in reduced hospital mortality and reduced need for ICU transfer.[37] However, other investigators have observed that imperfect implementation of nursing‐performed observational monitoring resulted in no demonstrable benefit, illustrating the limitations of this approach.[38] Our findings suggest that nursing care of patients on general hospital units may be enhanced with the use of an EWS alert sent to the RRT. This is supported by the observation that communications between the RRT and the primary care teams was greater as was the use of telemetry and oximetry in the intervention arm. Moreover, there appears to have been a learning effect for the nursing staff that occurred on our study units, as evidenced by the increased number of RRT calls that occurred between 2009 and 2013. This change in nursing practices on these units certainly made it more difficult for us to observe outcome differences in our current study with the prescribed intervention, reinforcing the notion that evaluating an already established practice is a difficult proposition.[39]

Our study has several important limitations. First, the EWS alert was developed and validated at Barnes‐Jewish Hospital.[11, 12, 13, 14] We cannot say whether this alert will perform similarly in another hospital. Second, the EWS alert only contains data from medical patients. Development and validation of EWS alerts for other hospitalized populations, including surgical and pediatric patients, are needed to make such systems more generalizable. Third, the primary clinical outcome employed for this trial was problematic. Transfer to an ICU may not be an optimal outcome variable, as it may be desirable to transfer alerted patients to an ICU, which can be perceived to represent a soft landing for such patients once an alert has been generated. A better measure could be 30‐day all‐cause mortality, which would not be subject to clinician biases. Finally, we could not specifically identify explanations for the greater use of antibiotics in the control group despite similar rates of infection for both study arms. Future studies should closely evaluate the ability of EWS alerts to alter specific therapies (eg, reduce antibiotic utilization).

In summary, we have demonstrated that an EWS alert linked to a RRT likely contributed to a modest reduction in hospital length of stay, but no reductions in hospital mortality and ICU transfer. These findings suggest that inpatient deterioration on general hospital units can be identified and linked to a specific intervention. Continued efforts are needed to identify and implement systems that will not only accurately identify high‐risk patients on general hospital units but also intervene to improve their outcomes. We are moving forward with the development of a 2‐tiered EWS utilizing both EMR data and real‐time streamed vital sign data, to determine if we can further improve the prediction of clinical deterioration and potentially intervene in a more clinically meaningful manner.

Acknowledgements

The authors thank Ann Doyle, BSN, Lisa Mayfield, BSN, and Darain Mitchell for their assistance in carrying out this research protocol; and William Shannon, PhD, from the Division of General Medical Sciences at Washington University, for statistical support.

Disclosures: This study was funded in part by the Barnes‐Jewish Hospital Foundation, the Chest Foundation of the American College of Chest Physicians, and by grant number UL1 RR024992 from the National Center for Research Resources (NCRR), a component of the National Institutes of Health (NIH), and NIH Roadmap for Medical Research. Its contents are solely the responsibility of the authors and do not necessarily represent the official view of the NCRR or NIH. The steering committee was responsible for the study design, execution, analysis, and content of the article. The Barnes‐Jewish Hospital Foundation, the American College of Chest Physicians, and the Chest Foundation were not involved in the design, conduct, or analysis of the trial. The authors report no conflicts of interest. Marin Kollef, Yixin Chen, Kevin Heard, Gina LaRossa, Chenyang Lu, Nathan Martin, Nelda Martin, Scott Micek, and Thomas Bailey have all made substantial contributions to conception and design, or acquisition of data, or analysis and interpretation of data; have drafted the submitted article or revised it critically for important intellectual content; have provided final approval of the version to be published; and have agreed to be accountable for all aspects of the work in ensuring that questions related to the accuracy or integrity of any part of the work are appropriately investigated and resolved.

Patients deemed suitable for care on a general hospital unit are not expected to deteriorate; however, triage systems are not perfect, and some patients on general nursing units do develop critical illness during their hospitalization. Fortunately, there is mounting evidence that deteriorating patients exhibit measurable pathologic changes that could possibly be used to identify them prior to significant adverse outcomes, such as cardiac arrest.[1, 2, 3] Given the evidence that unplanned intensive care unit (ICU) transfers of patients on general units result in worse outcomes than more controlled ICU admissions,[1, 4, 5, 6] it is logical to assume that earlier identification of a deteriorating patient could provide a window of opportunity to prevent adverse outcomes.

The most commonly proposed systematic solution to the problem of identifying and stabilizing deteriorating patients on general hospital units includes some combination of an early warning system (EWS) to detect the deterioration and a rapid response team (RRT) to deal with it.[7, 8, 9, 10] We previously demonstrated that a relatively simple hospital‐specific method for generating EWS alerts derived from the electronic medical record (EMR) database is capable of predicting clinical deterioration and the need for ICU transfer, as well as hospital mortality, in non‐ICU patients admitted to general inpatient medicine units.[11, 12, 13, 14] However, our data also showed that simply providing the EWS alerts to these nursing units did not result in any demonstrable improvement in patient outcomes.[14] Therefore, we set out to determine whether linking real‐time EWS alerts to an intervention and notification of the RRT for patient evaluation could improve the outcomes of patients cared for on general inpatient units.

METHODS

Study Location

The study was conducted on 8 adult inpatient medicine units of Barnes‐Jewish Hospital, a 1250‐bed academic medical center in St. Louis, MO (January 15, 2013May 9, 2013). Patient care on the inpatient medicine units is delivered by either attending hospitalist physicians or dedicated housestaff physicians under the supervision of an attending physician. Continuous electronic vital sign monitoring is not provided on these units. The study was approved by the Washington University School of Medicine Human Studies Committee, and informed consent was waived. This was a nonblinded study (ClinicalTrials.gov Identifier: NCT01741480).

Patients and Procedures

Patients admitted to the 8 medicine units received usual care during the study except as noted below. Manually obtained vital signs, laboratory data, and pharmacy data inputted in real time into the EMR were continuously assessed. The EWS searched for the 36 input variables previously described[11, 14] from the EMR for all patients admitted to the 8 medicine units 24 hours per day and 7 days a week. Values for every continuous parameter were scaled so that all measurements lay in the interval (0, 1) and were normalized by the minimum and maximum of the parameter as previously described.[14] To capture the temporal effects in our data, we retained a sliding window of all the collected data points within the last 24 hours. We then subdivided these data into a series of 6 sequential buckets of 4 hours each. We excluded the 2 hours of data prior to ICU transfer in building the model (so the data were 26 hours to 2 hours prior to ICU transfer for ICU transfer patients, and the first 24 hours of admission for everyone else). Eligible patients were selected for study entry when they triggered an alert for clinical deterioration as determined by the EWS.[11, 14]

The EWS alert was implemented in an internally developed, Java‐based clinical decision support rules engine, which identified when new data relevant to the model were available in a real‐time central data repository. In a clinical application, it is important to capture unusual changes in vital‐sign data over time. Such changes may precede clinical deterioration by hours, providing a chance to intervene if detected early enough. In addition, not all readings in time‐series data should be treated equally; the value of some kinds of data may change depending on their age. For example, a patient's condition may be better reflected by a blood‐oxygenation reading collected 1 hour ago than a reading collected 12 hours ago. This is the rationale for our use of a sliding window of all collected data points within the last 24 hours performed on a real‐time basis to determine the alert status of the patient.[11, 14]

We applied various threshold cut points to convert the EWS alert predictions into binary values and compared the results against the actual ICU transfer outcome.[14] A threshold of 0.9760 for specificity was chosen to achieve a sensitivity of approximately 40%. These operating characteristics were chosen in turn to generate a manageable number of alerts per hospital nursing unit per day (estimated at 12 per nursing unit per day). At this cut point, the C statistic was 0.8834, with an overall accuracy of 0.9292. In other words, our EWS alert system is calibrated so that for every 1000 patient discharges per year from these 8 hospital units, there would be 75 patients generating an alert, of which 30 patients would be expected to have the study outcome (ie, clinical deterioration requiring ICU transfer).

Once patients on the study units were identified as at risk for clinical deterioration by the EWS, they were assigned by a computerized random number generator to the intervention group or the control group. The control group was managed according to the usual care provided on the medicine units. The EWS alerts generated for the control patients were electronically stored, but these alerts were not sent to the RRT nurse, instead they were hidden from all clinical staff. The intervention group had their EWS alerts sent real time to the nursing member of the hospital's RRT. The RRT is composed of a registered nurse, a second‐ or third‐year internal medicine resident, and a respiratory therapist. The RRT was introduced in 2009 for the study units involved in this investigation. For 2009, 2010, and 2011 the RRT nurse was pulled from the staff of 1 of the hospital's ICUs in a rotating manner to respond to calls to the RRT as they occurred. Starting in 2012, the RRT nurse was established as a dedicated position without other clinical responsibilities. The RRT nurse carries a hospital‐issued mobile phone, to which the automated alert messages were sent real time, and was instructed to respond to all EWS alerts within 20 minutes of their receipt.

The RRT nurse would initially evaluate the alerted intervention patients using the Modified Early Warning Score[15, 16] and make further clinical and triage decisions based on those criteria and discussions with the RRT physician or the patient's treating physicians. The RRT focused their interventions using an internally developed tool called the Four Ds (discuss goals of care, drugs needing to be administered, diagnostics needing to be performed, and damage control with the use of oxygen, intravenous fluids, ventilation, and blood products). Patients evaluated by the RRT could have their current level of care maintained, have the frequency of vital sign monitoring increased, be transferred to an ICU, or have a code blue called for emergent resuscitation. The RRT reviewed goals of care for all patients to determine the appropriateness of interventions, especially for patients near the end of life who did not desire intensive care interventions. Nursing staff on the hospital units could also make calls to the RRT for patient evaluation at any time based on their clinical assessments performed during routine nursing rounds.

The primary efficacy outcome was the need for ICU transfer. Secondary outcome measures were hospital mortality and hospital length of stay. Pertinent demographic, laboratory, and clinical data were gathered prospectively including age, gender, race, underlying comorbidities, and severity of illness assessed by the Charlson comorbidity score and Elixhauser comorbidities.[17, 18]

Statistical Analysis

We required a sample size of 514 patients (257 per group) to achieve 80% power at a 5% significance level, based on the superiority design, a baseline event rate for ICU transfer of 20.0%, and an absolute reduction of 8.0% (PS Power and Sample Size Calculations, version 3.0, Vanderbilt Biostatistics, Nashville, TN). Continuous variables were reported as means with standard deviations or medians with 25th and 75th percentiles according to their distribution. The Student t test was used when comparing normally distributed data, and the Mann‐Whitney U test was employed to analyze non‐normally distributed data (eg, hospital length of stay). Categorical data were expressed as frequency distributions, and the [2] test was used to determine if differences existed between groups. A P value <0.05 was regarded as statistically significant. An interim analysis was planned for the data safety monitoring board to evaluate patient safety after 50% of the patients were recruited. The primary analysis was by intention to treat. Analyses were performed using SPSS version 11.0 for Windows (SPSS, Inc., Chicago, IL).

Data Safety Monitoring Board

An independent data safety and monitoring board was convened to monitor the study and to review and approve protocol amendments by the steering committee.

RESULTS

Between January 15, 2013 and May 9, 2013, there were 4731 consecutive patients admitted to the 8 inpatient units and electronically screened as the base population for this investigation. Five hundred seventy‐one (12.1%) patients triggered an alert and were enrolled into the study (Figure 1). There were 286 patients assigned to the intervention group and 285 assigned to the control group. No patients were lost to follow‐up. Demographics, reason for hospital admission, and comorbidities of the 2 groups were similar (Table 1). The number of patients having a separate RRT call by the primary nursing team on the hospital units within 24 hours of generating an alert was greater for the intervention group but did not reach statistical significance (19.9% vs 16.5%; odds ratio: 1.260; 95% confidence interval [CI]: 0.8231.931). Table 2 provides the new diagnostic and therapeutic interventions initiated within 24 hours after a EWS alert was generated. Patients in the intervention group were significantly more likely to have their primary care team physician notified by an RRT nurse regarding medical condition issues and to have oximetry and telemetry started, whereas control patients were significantly more likely to have new antibiotic orders written within 24 hours of generating an alert.

Figure 1
Study flow diagram. Abbreviations: ICU, intensive care unit.
Baseline Data
VariableIntervention Group, n=286Control Group, n=285P Value
Age, y63.7 16.063.1 15.40.495
Gender, n (%)   
Male132 (46.2)140 (49.1)0.503
Female154 (53.8)145 (50.9) 
Race, n (%)   
Caucasian155 (54.2)154 (54.0)0.417
African American105 (36.7)113 (39.6) 
Other26 (9.1)18 (6.3) 
Reason for hospital admission   
Cardiac12 (4.2)15 (5.3)0.548
Pulmonary64 (22.4)72 (25.3)0.418
Underlying malignancy6 (2.1)3 (1.1)0.504
Renal disease31 (10.8)22 (7.7)0.248
Thromboembolism4 (1.4)5 (1.8)0.752
Infection55 (19.2)50 (17.5)0.603
Neurologic disease33 (11.5)22 (7.7)0.122
Intra‐abdominal disease41 (14.3)47 (16.5)0.476
Hematologic condition4 (1.4)5 (1.8)0.752
Endocrine disorder12 (4.2)6 (2.1)0.153
Source of hospital admission   
Emergency department201 (70.3)203 (71.2)0.200
Direct admission36 (12.6)46 (16.1) 
Hospital transfer49 (17.1)36 (12.6) 
Charlson score6.7 3.66.6 3.20.879
Elixhauser comorbidities score7.4 3.57.5 3.40.839
Diagnostic and Therapeutic Interventions Initiated Within 24 Hours of Generating an Alert
VariableIntervention Group, n=286Control Group, n=285P Value
  • NOTE: Abbreviations: RRT, rapid response team.

Medications, n (%)   
Antibiotics92 (32.2)121 (42.5)0.011
Antiarrhythmics48 (16.8)44 (15.4)0.662
Anticoagulants83 (29.0)97 (34.0)0.197
Diuretics/antihypertensives71 (24.8)55 (19.3)0.111
Bronchodilators78 (27.3)73 (25.6)0.653
Anticonvulsives26 (9.1)27 (9.5)0.875
Sedatives/narcotics0 (0.0)1 (0.4)0.499
Respiratory support, n (%)   
Noninvasive ventilation17 (6.0)9 (3.1)0.106
Escalated oxygen support12 (4.2)7 (2.5)0.247
Enhanced vital signs, n (%)50 (17.5)47 (16.5)0.752
Maintenance intravenous fluids, n (%)48 (16.8)41 (14.4)0.430
Vasopressors, n (%)57 (19.9)61 (21.4)0.664
Bolus intravenous fluids, n (%)7 (2.4)14 (4.9)0.118
Telemetry, n (%)198 (69.2)176 (61.8)0.052
Oximetry, n (%)20 (7.0)6 (2.1)0.005
New intravenous access, n (%)26 (9.1)35 (12.3)0.217
Primary care team physician called by RRT nurse, n (%)82 (28.7)56 (19.6)0.012

Fifty‐one patients (17.8%) randomly assigned to the intervention group required ICU transfer compared with 52 of 285 patients (18.2%) in the control group (odds ratio: 0.972; 95% CI: 0.6351.490; P=0.898) (Table 3). Twenty‐one patients (7.3%) randomly assigned to the intervention group expired during their hospitalization compared with 22 of 285 patients (7.7%) in the control group (odds ratio: 0.947; 95%CI: 0.5091.764; P=0.865). Hospital length of stay was 8.49.5 days (median, 4.5 days; interquartile range, 2.311.4 days) for patients randomized to the intervention group and 9.411.1 days (median, 5.3 days; interquartile range, 3.211.2 days) for patients randomized to the control group (P=0.038). The ICU length of stay was 4.86.6 days (median, 2.9 days; interquartile range, 1.76.5 days) for patients randomized to the intervention group and 5.86.4 days (median, 2.9 days; interquartile range, 1.57.4) for patients randomized to the control group (P=0.812).The number of patients requiring transfer to a nursing home or long‐term acute care hospital was similar for patients in the intervention and control groups (26.9% vs 26.3%; odds ratio: 1.032; 95% CI: 0.7121.495; P=0.870). Similarly, the number of patients requiring hospital readmission before 30 days and 180 days, respectively, was similar for the 2 treatment groups (Table 3). For the combined study population, the EWS alerts were triggered 94138 hours (median, 27 hours; interquartile range, 7132 hours) prior to ICU transfer and 250204 hours (median200 hours; interquartile range, 54347 hours) prior to hospital mortality. The number of RRT calls for the 8 medicine units studied progressively increased from the start of the RRT program in 2009 through 2013 (121 in 2009, 194 in 2010, 298 in 2011, 415 in 2012, 415 in 2013; P<0.001 for the trend).

Outcomes
OutcomeIntervention Group, n=286Control Group, n=285P Value
  • NOTE: Abbreviations: ICU, intensive care unit; LTAC, long‐term acute care. *Values expressed as meanstandard deviation, median [interquartile range].

ICU transfer, n (%)51 (17.8)52 (18.2)0.898
All‐cause hospital mortality, n (%)21 (7.3)22 (7.7)0.865
Transfer to nursing home or LTAC, n (%)77 (26.9)75 (26.3)0.870
30‐day readmission, n (%)53 (18.5)62 (21.8)0.337
180‐day readmission, n (%)124 (43.4)117 (41.1)0.577
Hospital length of stay, d*8.49.5, 4.5 [2.311.4]9.411.1, 5.3 [3.211.2]0.038
ICU length of stay, d*4.86.6, 2.9 [1.76.5]5.86.4, 2.9 [1.57.4]0.812

DISCUSSION

We demonstrated that a real‐time EWS alert sent to a RRT nurse was associated with a modest reduction in hospital length of stay, but similar rates of hospital mortality, ICU transfer, and subsequent need for placement in a long‐term care setting compared with usual care. We also found the number of RRT calls to have increased progressively from 2009 to the present on the study units examined.

Unplanned ICU transfers occurring as early as within 8 hours of hospitalization are relatively common and associated with increased mortality.[6] Bapoje et al. evaluated a total of 152 patients over 1 year who had unplanned ICU transfers.[19] The most common reason was worsening of the problem for which the patient was admitted (48%). Other investigators have also attempted to identify predictors for clinical deterioration resulting in unplanned ICU transfer that could be employed in an EWS.[20, 21] Organizations like the Institute for Healthcare Improvement have called for the development and routine implementation of EWSs to direct the activities of RRTs and improve outcomes.[22] However, a recent systematic review found that much of the evidence in support of EWSs and emergency response teams is of poor quality and lacking prospective randomized trials.[23]

Our earlier experience demonstrated that simply providing an alert to nursing units did not result in any demonstrable improvements in the outcomes of high‐risk patients identified by our EWS.[14] Previous investigations have also had difficulty in demonstrating consistent outcome improvements with the use of EWSs and RRTs.[24, 25, 26, 27, 28, 29, 30, 31, 32] As a result of mandates from quality improvement organizations, most US hospitals currently employ RRTs for emergent mobilization of resources when a clinically deteriorating patient is identified on a hospital ward.[33, 34] Linking RRT actions with a validated real‐time alert may represent a way of improving the overall effectiveness of such teams for monitoring general hospital units, short of having all hospitalized patients in units staffed and monitored to provide higher levels of supervision (eg, ICUs, step‐down units).[9, 35]

An alternative approach to preventing patient deterioration is to provide closer overall monitoring. This has been accomplished by employing nursing personnel to increase monitoring, or with the use of automated monitoring equipment. Bellomo et al. showed that the deployment of electronic automated vital sign monitors on general hospital units was associated with improved utilization of RRTs, increased patient survival, and decreased time for vital sign measurement and recording.[36] Laurens and Dwyer found that implementation of medical emergency teams (METs) to respond to predefined MET activation criteria as observed by hospital staff resulted in reduced hospital mortality and reduced need for ICU transfer.[37] However, other investigators have observed that imperfect implementation of nursing‐performed observational monitoring resulted in no demonstrable benefit, illustrating the limitations of this approach.[38] Our findings suggest that nursing care of patients on general hospital units may be enhanced with the use of an EWS alert sent to the RRT. This is supported by the observation that communications between the RRT and the primary care teams was greater as was the use of telemetry and oximetry in the intervention arm. Moreover, there appears to have been a learning effect for the nursing staff that occurred on our study units, as evidenced by the increased number of RRT calls that occurred between 2009 and 2013. This change in nursing practices on these units certainly made it more difficult for us to observe outcome differences in our current study with the prescribed intervention, reinforcing the notion that evaluating an already established practice is a difficult proposition.[39]

Our study has several important limitations. First, the EWS alert was developed and validated at Barnes‐Jewish Hospital.[11, 12, 13, 14] We cannot say whether this alert will perform similarly in another hospital. Second, the EWS alert only contains data from medical patients. Development and validation of EWS alerts for other hospitalized populations, including surgical and pediatric patients, are needed to make such systems more generalizable. Third, the primary clinical outcome employed for this trial was problematic. Transfer to an ICU may not be an optimal outcome variable, as it may be desirable to transfer alerted patients to an ICU, which can be perceived to represent a soft landing for such patients once an alert has been generated. A better measure could be 30‐day all‐cause mortality, which would not be subject to clinician biases. Finally, we could not specifically identify explanations for the greater use of antibiotics in the control group despite similar rates of infection for both study arms. Future studies should closely evaluate the ability of EWS alerts to alter specific therapies (eg, reduce antibiotic utilization).

In summary, we have demonstrated that an EWS alert linked to a RRT likely contributed to a modest reduction in hospital length of stay, but no reductions in hospital mortality and ICU transfer. These findings suggest that inpatient deterioration on general hospital units can be identified and linked to a specific intervention. Continued efforts are needed to identify and implement systems that will not only accurately identify high‐risk patients on general hospital units but also intervene to improve their outcomes. We are moving forward with the development of a 2‐tiered EWS utilizing both EMR data and real‐time streamed vital sign data, to determine if we can further improve the prediction of clinical deterioration and potentially intervene in a more clinically meaningful manner.

Acknowledgements

The authors thank Ann Doyle, BSN, Lisa Mayfield, BSN, and Darain Mitchell for their assistance in carrying out this research protocol; and William Shannon, PhD, from the Division of General Medical Sciences at Washington University, for statistical support.

Disclosures: This study was funded in part by the Barnes‐Jewish Hospital Foundation, the Chest Foundation of the American College of Chest Physicians, and by grant number UL1 RR024992 from the National Center for Research Resources (NCRR), a component of the National Institutes of Health (NIH), and NIH Roadmap for Medical Research. Its contents are solely the responsibility of the authors and do not necessarily represent the official view of the NCRR or NIH. The steering committee was responsible for the study design, execution, analysis, and content of the article. The Barnes‐Jewish Hospital Foundation, the American College of Chest Physicians, and the Chest Foundation were not involved in the design, conduct, or analysis of the trial. The authors report no conflicts of interest. Marin Kollef, Yixin Chen, Kevin Heard, Gina LaRossa, Chenyang Lu, Nathan Martin, Nelda Martin, Scott Micek, and Thomas Bailey have all made substantial contributions to conception and design, or acquisition of data, or analysis and interpretation of data; have drafted the submitted article or revised it critically for important intellectual content; have provided final approval of the version to be published; and have agreed to be accountable for all aspects of the work in ensuring that questions related to the accuracy or integrity of any part of the work are appropriately investigated and resolved.

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  26. Ball C, Kirkby M, Williams S. Effect of the critical care outreach team on patient survival to discharge from hospital and readmission to critical care: non‐randomised population based study. BMJ. 2003;327(7422):1014.
  27. Hatlem T, Jones C, Woodard EK. Reducing mortality and avoiding preventable ICU utilization: analysis of a successful rapid response program using APR DRGs. J Healthc Qual. 2011;33(5):716.
  28. Hillman K, Chen J, Cretikos M, et al. Introduction of the medical emergency team (MET) system: a cluster‐randomised control trial. Lancet. 2005;365(9477):20912097.
  29. Gao H, Harrison DA, Parry GJ, Daly K, Subbe CP, Rowan K. The impact of the introduction of critical care outreach services in England: a multicentre interrupted time‐series analysis. Crit Care. 2007;11(5):R113.
  30. Gao H, McDonnell A, Harrison DA, et al. Systematic review and evaluation of physiological track and trigger warning systems for identifying at‐risk patients on the ward. Intensive Care Med. 2007;33(4):667679.
  31. Peebles E, Subbe CP, Hughes P, Gemmell L. Timing and teamwork—an observational pilot study of patients referred to a Rapid Response Team with the aim of identifying factors amenable to re‐design of a Rapid Response System. Resuscitation. 2012;83(6):782787.
  32. Karpman C, Keegan MT, Jensen JB, Bauer PR, Brown DR, Afessa B. The impact of rapid response team on outcome of patients transferred from the ward to the ICU: a single‐center study. Crit Care Med. 2013;41(10):22842291.
  33. Prado R, Albert RK, Mehler PS, Chu ES. Rapid response: a quality improvement conundrum. J Hosp Med. 2009;4(4):255257.
  34. Schneider ME. Rapid response systems now established at 2,900 hospitals. Hospitalist News. 2010;3:1.
  35. Geogaka D, Mparmparousi M, Vitos M. Early warning systems. Hosp Chron. 2012;7:3743.
  36. Bellomo R, Ackerman M, Bailey M, et al. A controlled trial of electronic automated advisory vital signs monitoring in general hospital wards. Crit Care Med. 2012;40(8):23492361.
  37. Laurens N, Dwyer T. The impact of medical emergency teams on ICU admission rates, cardiopulmonary arrests and mortality in a regional hospital. Resuscitation. 2011;82(6):707712.
  38. Niegsch M, Fabritius ML, Anhoj J. Imperfect implementation of an early warning scoring system in a danish teaching hospital: a cross‐sectional study. PLoS One. 2013;8:e70068.
  39. England K, Bion JF. Introduction of medical emergency teams in Australia and New Zealand: A multicentre study. Crit Care. 2008;12(3):151.
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  25. Pittard AJ. Out of our reach? Assessing the impact of introducing critical care outreach service. Anaesthesiology. 2003;58(9):882885.
  26. Ball C, Kirkby M, Williams S. Effect of the critical care outreach team on patient survival to discharge from hospital and readmission to critical care: non‐randomised population based study. BMJ. 2003;327(7422):1014.
  27. Hatlem T, Jones C, Woodard EK. Reducing mortality and avoiding preventable ICU utilization: analysis of a successful rapid response program using APR DRGs. J Healthc Qual. 2011;33(5):716.
  28. Hillman K, Chen J, Cretikos M, et al. Introduction of the medical emergency team (MET) system: a cluster‐randomised control trial. Lancet. 2005;365(9477):20912097.
  29. Gao H, Harrison DA, Parry GJ, Daly K, Subbe CP, Rowan K. The impact of the introduction of critical care outreach services in England: a multicentre interrupted time‐series analysis. Crit Care. 2007;11(5):R113.
  30. Gao H, McDonnell A, Harrison DA, et al. Systematic review and evaluation of physiological track and trigger warning systems for identifying at‐risk patients on the ward. Intensive Care Med. 2007;33(4):667679.
  31. Peebles E, Subbe CP, Hughes P, Gemmell L. Timing and teamwork—an observational pilot study of patients referred to a Rapid Response Team with the aim of identifying factors amenable to re‐design of a Rapid Response System. Resuscitation. 2012;83(6):782787.
  32. Karpman C, Keegan MT, Jensen JB, Bauer PR, Brown DR, Afessa B. The impact of rapid response team on outcome of patients transferred from the ward to the ICU: a single‐center study. Crit Care Med. 2013;41(10):22842291.
  33. Prado R, Albert RK, Mehler PS, Chu ES. Rapid response: a quality improvement conundrum. J Hosp Med. 2009;4(4):255257.
  34. Schneider ME. Rapid response systems now established at 2,900 hospitals. Hospitalist News. 2010;3:1.
  35. Geogaka D, Mparmparousi M, Vitos M. Early warning systems. Hosp Chron. 2012;7:3743.
  36. Bellomo R, Ackerman M, Bailey M, et al. A controlled trial of electronic automated advisory vital signs monitoring in general hospital wards. Crit Care Med. 2012;40(8):23492361.
  37. Laurens N, Dwyer T. The impact of medical emergency teams on ICU admission rates, cardiopulmonary arrests and mortality in a regional hospital. Resuscitation. 2011;82(6):707712.
  38. Niegsch M, Fabritius ML, Anhoj J. Imperfect implementation of an early warning scoring system in a danish teaching hospital: a cross‐sectional study. PLoS One. 2013;8:e70068.
  39. England K, Bion JF. Introduction of medical emergency teams in Australia and New Zealand: A multicentre study. Crit Care. 2008;12(3):151.
Issue
Journal of Hospital Medicine - 9(7)
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Journal of Hospital Medicine - 9(7)
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424-429
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424-429
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A randomized trial of real‐time automated clinical deterioration alerts sent to a rapid response team
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A randomized trial of real‐time automated clinical deterioration alerts sent to a rapid response team
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Address for correspondence and reprint requests: Marin Kollef, MD, Division of Pulmonary and Critical Care Medicine, Washington University School of Medicine, 660 South Euclid Avenue, Campus Box 8052, St. Louis, MO 63110; Telephone: 314‐454‐8764; Fax: 314‐454‐5571; E‐mail: [email protected]
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