[go: up one dir, main page]
More Web Proxy on the site http://driver.im/ Skip to main content
Journal of Healthcare Informatics Research logoLink to Journal of Healthcare Informatics Research
. 2021 Jan 27;5(3):300–318. doi: 10.1007/s41666-021-00091-x

A Cross-Sectional Study to Predict Mortality for Medicare Patients Based on the Combined Use of HCUP Tools

Dimitrios Zikos 1,, Aashara Shrestha 2, Leonidas Fegaras 2
PMCID: PMC8982697  PMID: 35419505

Abstract

Prediction of inpatient mortality is not an easy problem since multiple comorbidities and other factors in synergy have a variable effect on inpatient death risk. This research combined Healthcare Cost and Utilization Project (HCUP) tools (clinical classification software, CCS; Chronic Condition Indicator, CCI) to recommend a critical set of CCS diagnosis and procedure predictors for mortality. The study motivation is to provide the research community an up-to-date critical set of inhospital mortality predictors. The study follows a cross-sectional design. An inpatient CMS claims file (N = 418,529) was combined with the HCUP grouper to transform the ICD-10-CM and CPT codes to CCS categories and to enhance the data with the acuity and the diagnosis presence/non-presence on admission. Five logistic regressions were conducted to progressively enhance the feature set with the aforementioned dimensions. The Sensitivitydeath and positive predictive value (PPVdeath) were estimated for each consecutive step to examine the attributable predictive power of each dimension. When all information were inserted, the PPVdeath was 65.5%, a 10% increase over a single representation of secondary diagnoses. A critical collection of significant CCS diagnoses and procedures were extracted as predictors of inpatient mortality. The chronicity and POA status of a diagnosis improve the prediction of inpatient mortality. Furthermore, the combined use of these dimensions provides better predictions against the Elixhauser Comorbidity Index. The combined use of HCUP tools provides a reasonable estimate of inpatient mortality. This is the first study that uses the updated HCUP groupers for ICD-10-CM to provide insights about drivers of inpatient mortality.

Keywords: Comorbidities, Inpatient mortality, Prediction, Medicare, HCUP

Background and Significance

Many studies explain the methods for the prediction of inpatient mortality for patients admitted with acute conditions [1, 2] and discuss data challenges for the prediction of this outcome [3]. Since inpatient mortality is an important metric for quality assessment and external reporting, it is oftentimes studied as a baseline to measure the predictive performance of clinical analytics. The prediction of short-term hospital mortality is not an easy problem. Due to the probabilistic nature of healthcare, similar patients may differ in terms of outcomes. Awad et al. summarized publications between the years 1984 and 2016 that discuss the prediction of mortality [4]. Variations to the risk for negative outcomes of care, such as death, can be warranted, due to inherent clinical characteristics and disease complexity, or unwarranted, due to modifiable factors [5]. Objectively, severe case mixes are at higher risk for hospital death, while at the same time, several hospital structure attributes, such as hospital volume [6, 7], can influence the risk for hospital death.

To examine inpatient mortality, critical variables of the study include the principal diagnosis, the secondary diagnoses that may or may not be associated with the reason for hospitalization (complications and comorbidities), and medical procedures, as well as the age-associated risk [8]. Other hospital mortality predictors have been reported to be various disease-specific laboratory test results [9].

Hospital-acquired conditions, the presence of chronic conditions, and several medical procedures can also be associated with an increased risk for hospital death. Morsy et al. found that the development of bacterial infection, shock, early rebreeding, low serum albumin, low baseline hemoglobin, and the need for endoscopic treatment were independent risk factors of hospital mortality among cirrhotic patients [10]. Other information that can be associated with the risk for hospital death is whether the patient was a readmission case [11] and was directly transferred from a different hospital, as well as the urgency of hospital admission.

Several disease dimensions are important for the thorough study of inpatient mortality. Researchers should be able to distinguish between principal and secondary diagnoses. Studies could also benefit from characterizing the secondary diagnoses as of chronic or acute nature and as hospital-acquired or preexisting. These secondary diagnosis dimensions can contribute to improved predictive performance for inpatient outcomes research.

Beginning in 2015, hospitals in the USA started to use the 10th edition of the clinical modification of the International Classification of Diseases (ICD-10-CM). ICD-10-CM provides a great level of specificity since it includes more than 69,000 unique codes. On the other hand, its out-of-the-box appropriateness in predictive analytics can be problematic for several reasons. Firstly, with such an enormous feature set, the risk for overfitting is high, unless many millions of data records are available. Additionally, when enormous data matrices are analyzed, there is a substantial increase in computational complexity. The clinical classification software (CCS) was developed by the Healthcare Cost and Utilization Project (HCUP) and classifies the thousands of ICD-10-CM and ICD-10-PCS codes into 285 diagnostic and 231 procedure categories. CCS, therefore, provides a compact representation of the medical diagnoses and procedures [12]. In 2016, HCUP released updated versions that are compatible with the 10th editions of ICD-CM and ICD-PCS. Besides, HCUP makes available the Chronic Condition Indicator (CCI), to classify each ICD-10-CM code as chronic or non-chronic [13].

While CCS is a well-studied approach to manually reduce the dimensionality of medical diagnoses [14, 15], other methods include the use of comorbidity indexes. One of these indexes is the Elixhauser Comorbidity Index, which extracts patient comorbidities from the ICD and diagnosis-related group (DRG) codes found in administrative data. The index has been used in hospital outcomes research such as in [16], to predict hospital resource use and hospital mortality. The most recent edition of the index includes 29 categories and is compatible with ICD-10-CM. The Centers for Medicare and Medicaid Services (CMS) provides medical claim datasets to researchers; the HCUP tools can be combined with these datasets since they use the ICD-10-CM and ICD-10-CPT classification systems to represent the clinical diagnoses and procedures.

Objective

The motivation for the present study is to improve the predictive capacity of medical claims data, by extracting and utilizing meaningful dimensions of diagnoses from HCUP tools and other available metadata. The research hypothesis is that the combined use of medical claims data with the HCUP tools (ICD to CCS and ICD to CCI grouper) and other metadata (“present on admission” indicator) can enrich the information about medical conditions, reducing information entropy and therefore improving the capacity to predict the outcome of hospital mortality. To the authors’ knowledge, this is the first study that examines the combined use of the updated (ICD-10 edition) HCUP tools with medical claims data, for inpatient outcomes research.

This study aims to (i) examine the predictive power of the combined use of the HCUP tools and medical claims data for the outcome of inpatient mortality, among Medicare patients, (ii) compare the predictive performance of the recommended secondary diagnosis dimensions against the use of the Elixhauser Comorbidity Index, and (iii) recommend a statistically significant collection of critical CCS diagnosis and procedure predictors for inpatient mortality.

With this work, the authors want to provide to the research community a meaningful reduced multidimensional CCS diagnostic code set to facilitate future research effort that uses HCUP and CMS inpatient databases. This set includes statistically significant predictors. Besides, the statistical model that was developed to extract these statistically significant variables can easily be replicated in future research efforts. This is important since HCUP and CMS databases are frequently utilized in health data science research studies. The motivation is to evaluate the use of the updated HCUP tools on recent inpatient CMS data and provide a set of comorbidities, including chronic and hospital-acquired conditions that increase the likelihood of death, while the study of mortality, in general, would benefit from additional predictors, some of which may be condition-specific and not examined in the current research. The study provides a multidimensional set of high-risk diagnoses for inpatient death by making the distinction as a hospital or nonhospital acquired, chronic, or acute. While the HCUP tools have been used for risk adjustment by other studies, no research relies on the updated CCS to ICD-10 mapping, and this is a contribution of this work: apparently, regrouping diagnostic codes under CCS buckets, with the 10th ICD edition, which follows a different philosophy from ICD-9-CM, may result in CCS groups different from the ones that an ICD-9-CM dataset would generate.

Materials and Methods

Data Sources and Data Preparation

The study was completed with an inpatient “limited dataset” (LDS) from the CMS which includes every inpatient Medicare admission in Michigan during the year 2016 (N = 418,529). The dataset contains information about the beneficiary (age, gender, ethnicity), admission information (source and type of admission), the clinical diagnoses (principal and secondary) in ICD-10-CM format, present on admission (POA) indicators for each diagnosis, the medical procedures in ICD-10-PCS format, the patient discharge status, disposition information, and DRG information.

The dataset also contains tags that specify whether the diagnosis has been POA or not. This tag makes it possible for researchers to extract hospital-acquired conditions. Diagnoses (such as a bacterial infection) were chosen to be differentiated as hospital/nonhospital acquired due to the differences to disease management when a condition is identified in-hospital, and also since hospital-acquired bacterial infections are oftentimes antibiotic-resistant (such as the methicillin-resistant Staphylococcus aureus), and therefore not as easy to treat. A dichotomous “hospital death” variable was created from the discharge status variable. Each of the ICD-10-CM codes was characterized as chronic or non-chronic, using the HCUP CCI grouper. CCΙ was designed by HCUP to categorize ICD-10-CM diagnostic codes into a category of “chronic” or “not chronic.”

After this, every ICD-10-CM and ICD-10-PCS code was replaced with their corresponding CCS codes. To transform the diagnosis and procedure attributes from the ICD into the CCS coding system, a crosswalk, publicly available from AHRQ, was used. As expected, after this binning was completed, the same CCS code can have a chronic or a non-chronic CCI characterization across the dataset, since it could have derived from different ICD codes.

Apparently, for this study, principal diagnoses have been differentiated from the secondary diagnostic codes: a separate variable was generated for the principal diagnosis information. A total of 285 dichotomous variables (one per CCS code) suggest the presence or not of each CCS code as a secondary diagnosis. The dataset was also enriched with another collection of 285 dichotomous variables that specify the POA status of each secondary diagnosis. Finally, a collection of 285 variables specify the chronicity of each secondary diagnosis. Similarly, 231 dichotomous variables were created, one for each CCS procedure code. Table 1 shows the new variables after all transformations.

Table 1.

Data sources, transformed variables, and attributes

Original data that the study combined Transformed variables

LDS inpatient dataset: principal diagnosis (ICD-10-CM)

ICD-10-CM to CCS grouper: ICD-10-CM to CCS mapping

Principal diagnoses in CCS format (285 unique CCS codes)

LDS inpatient dataset: secondary diagnosis variables

ICD-10-CM to CCS grouper: ICD-10-CM to CCS mapping

285 secondary diagnostic dichotomous variables (in CCS)

LDS inpatient dataset: secondary diagnosis variables (ICD-10-CM)

LDS inpatient dataset: matching “present on admission” (POA) indicator per each secondary diagnosis variable

ICD-10-CM to CCS grouper: ICD-10-CM to CCS mapping

285 dichotomous variables specifying whether each secondary diagnosis was POA or not

CCI grouper: chronic condition indicator to ICD-10 mapping

LDS inpatient dataset: secondary diagnosis variables

285 dichotomous variables specifying whether each secondary diagnosis is chronic or not

LDS in-patient dataset: medical procedures in ICD10-CPT format

ICD-10-PCS to CCS grouper: ICD-10-PCS to CCS mapping

231 dichotomous medical procedure variables (in CCS)

With these data transformations, four dimensions of a diagnostic code became available: (1) the principal diagnosis, in CCS format; (2) the secondary diagnoses, in CCS format; (3) the chronicity of each secondary diagnosis; and (4) the dichotomous present on admission information for each secondary diagnosis. The work is conceptually novel in that it (i) differentiates diagnoses as chronic versus non-chronic, based on the HCUP CCI tool for ICD-10-CM; (ii) differentiates diagnoses as hospital-acquired or not, based on the POA indicator and consequently groups them into CCS using the new mapping; and (iii) compares the proposed set of top CCS mortality predictors as an alternative to the Elixhauser index, for inpatient mortality research.

Design

The study follows a cross-sectional design. The outcome of inpatient death is examined with multivariate binary logistic regression (BLR) to estimate the combined predictive power of the HCUP-deriving dimensions under study. Five consecutive regression runs were conducted. In each consecutive step, additional information was added to the model. The variables were inserted into each model using the enter method. The baseline predictors (step 0) include the age group, gender, the “transfer from another hospital” indicator, and the urgency of admission. In the dataset, an admission labeled as “emergency” is a hospital admission that occurred after the ER visit or after calling an ambulance. In step 1, the principal diagnosis information was inserted into the model. In step 2, the secondary diagnosis codes were also inserted. In step 3, the variables that represent the CCS chronicity were added, while, in step 4, the POA variables were inserted into the model. Finally, in step 5, the CCS procedures were inserted on top of the aforementioned diagnosis dimensions. By comparing the Sensitivitydeath and PPVdeath of the five models, the study will estimate the contribution of each dimension to the prediction of hospital death. The Sensitivitydeath and PPVdeath of step 5 were also compared with those of Naïve Bayes (NB), which is often used as a baseline classifier in predictive analytics, to establish the “starting point” of developing better performing models. This is because NB does not examine interactions between the independent variables against the outcome under study. Interestingly, classifiers that rely on the Bayesian theorem seem to work surprisingly well in many clinical problems, probably due to the probabilistic nature of health and disease. By calculating the odds ratios of step 5, this study will finally recommend a list of critical clinical diagnoses and procedures that increase or decrease the likelihood of inpatient death in a statistically significant way [17]. Due to the large volume of the target dataset, a significance level of 0.01 was used in the statistical analysis tasks. The regression analysis was conducted with SPSS version 24 (IBM Corp., 2016). The comparison of the predictive performance between BLR and NB was performed with Weka data mining software, version 3.9. Figure 1 presents an overview of the research design.

Fig. 1.

Fig. 1

Overview of the research design

Results

Prediction of Hospital Mortality

In the baseline model (step 0), no diagnosis or procedure information was used as a predictor of inpatient mortality. The independent variables (IV) were the admission information (transfer from another hospital, the urgency of admission) and the main demographics (age group, gender). Both the Sensitivitydeath and PPVdeath were found to be 0%. This means that using these baseline variables as predictors, all hospital death cases were incorrectly misclassified as alive. In step 1, on top of the baseline information, the principal diagnosis is inserted into the list of IVs. The Sensitivitydeath was only .9%, and the PPVdeath was found to be 54.34%. The Nagelkerke pseudo R2 statistic was equal to .157, meaning that the IVs inserted into the step 1 model only explained 15.7% of inpatient mortality. In step 2, in addition to step 1 IVs, the secondary diagnoses were also inserted. The Sensitivitydeath was now increased to 24.9%, and the PPVdeath was equal to 62.66%. The Nagelkerke R2 statistic was also increased to .439. In step 3, the POA information of the secondary diagnoses was also inserted into the model. The Sensitivitydeath was increased to 28.4%, the PPVdeath to 65.14%, and the Nagelkerke R2 statistic to .461. In step 4, on top of the step 3 variables, the variables specifying the chronicity status of secondary diagnoses were inserted. The Sensitivitydeath was slightly increased to 29.3%, the PPVdeath remained unchanged (65.14%), and the Nagelkerke R2 statistic was slightly increased to .469. Finally, step 5 included every IV previously inserted in step 4 and, additionally, the clinical procedures. The Sensitivitydeath and the PPVdeath were both increased to 34.1% and 68.04%, respectively. The Nagelkerke R2 statistic was also increased by almost 3% in comparison to step 4.

Following these experiments, the performance of BLR was compared against NB, for each of the five aforementioned steps. NB is an algorithm based on Bayesian probabilities and is widely used in clinical modeling, despite its drawback of assuming independence of the IVs. The Sensitivitydeath, PPVdeath, and F-measuredeath were estimated for each of the five steps (Fig. 2). According to the results, when all dimensions are inserted (step 5), BLR outperforms NB in terms of PPVdeath, but NB significantly outperforms BLR in terms of Sensitivitydeath: if the objective is to miss as few inpatient deaths as possible, without false positives being an issue, the use of Bayesian predictive methods such as NB may be preferred for the prediction of inpatient mortality.

Fig. 2.

Fig. 2

Sensitivitydeath, PPVdeath, and F-measuredeath comparison of BLR vs. Naïve Bayes. Binary logistic regression using enter method, Naïve Bayes with default parameters. Nagelkerke pseudo R2 for step 5 = 0.497

Factors Associated with Hospital Death

By studying the statistically significant variables of step 5, several patient attributes, principal and secondary diagnoses, and medical procedures were found to be associated with an increase or a decrease in the likelihood of hospital death. Additional variables from the new dimensions that this research created (chronicity, presence on admission) were also found to be associated with inpatient death.

Older age groups and the transfer from another hospital indicator were found to be associated with an increased likelihood of hospital death. With the age group of <65 years being the reference category, the 65–69 years old group was found to be associated with a 26% increase in the likelihood of inpatient death (OR = 1.26, 1.14–1.38). For the age group of 70–74, the OR is higher, at 1.47 (1.33–1.62), and becomes even higher for the age group of 75–79 (OR = 1.64, 1.48–1.81), the 80–84 years old group (OR = 2.12, 1.91–2.35), and the >84 years old group (OR = 2.80, 2.5–3.10). Besides, when a patient is transferred from another hospital, the likelihood of inpatient death increases by 50% (OR = 1.50, 1.37–1.63).

Eleven principal diagnoses were found to be associated with an increased likelihood of inpatient death. On the other hand, no principal diagnosis was negatively associated with inpatient death. A total of 31 secondary diagnoses were positive predictors of inpatient death, while 28 secondary diagnoses were associated with a decreased likelihood for inpatient death. Seventeen non-POA secondary diagnoses were found to be statistically positive significant predictors of death; 13 non-POA secondary diagnoses were negatively associated with inpatient death. Several chronic conditions increase (N = 8) or decrease (N = 10) the likelihood of inpatient death. Finally, several medical procedures were found to be associated with an increased (N = 7) or a decreased (N = 20) likelihood of inpatient death (Tables 2 and 3).

Table 2.

Factors positively associated with inpatient death

CCS code CCS description OR CI
Principal diagnosis
CCS = 20 Cancer, other respiratory 69.09 6.67–715.96
CCS = 31 Male genital organ cancer 65.09 3.03–1396.2
CCS = 107 Cardiac arrest 20.68 2.75–155.30
CCS = 240 Burns 17.19 1.73–170.36
CCS = 166 Male genital disorders 16.03 1.34–191.91
CCS = 40 Multiple myeloma 12.68 1.60–100.28
CCS = 39 Leukemia 11.51 1.50–88.39
CCS = 24 Cancer of breast 11.27 1.36–93.11
CCS = 38 Non-Hodgkin’s lymphoma 11.05 1.44–84.87
CCS = 249 Shock 8.83 1.16–67.05
CCS = 109 Acute cerebrovascular disease 8.26 1.12–60.90
Secondary diagnosis
CCS = 156 Nephritis/renal sclerosis 6.70 1.98–22.62
CCS = 107 Cardiac arrest 4.49 3.82–5.28
CCS = 85 Coma; stupor; brain damage 4.46 3.80–5.22
CCS = 249 Shock 3.53 3.24–3.84
CCS = 114 Peripheral and visceral atherosclerosis 2.76 1.97–3.85
CCS = 131 Respiratory failure; arrest 2.48 2.30–2.67
CCS = 259 Residual codes 2.27 2.14–2.40
CCS = 42 Secondary malignancies 1.96 1.74–2.20
CCS = 257 Other aftercare 1.89 1.79–1.99
CCS = 148 Peritonitis/intestinal abscess 1.82 1.43–2.31
CCS = 43 Malignant neoplasm without specification of site 1.61 1.15–2.26
CCS = 226 Fracture of neck of femur (hip) 1.60 1.13–2.26
CCS = 151 Other liver diseases 1.54 1.39–1.71
CCS = 44 Neoplasms of unspec. nature or uncertain behavior 1.54 1.21–1.95
CCS = 40 Multiple myeloma 1.53 1.15–2.01
CCS = 145 Intestinal obstruction without hernia 1.51 1.29–1.78
CCS = 2 Septicemia (except in labor) 1.46 1.33–1.61
CCS = 157 Acute and unspecified renal failure 1.43 1.34–1.52
CCS = 55 Fluid and electrolyte disorders 1.37 1.29–1.45
CCS = 233 Intracranial injury 1.37 1.10–1.69
CCS = 52 Nutritional deficiencies 1.35 1.19–1.53
CCS = 153 Gastrointestinal hemorrhage 1.33 1.15–1.54
CCS = 100 Acute myocardial infraction 1.32 1.19–1.47
CCS = 199 Chronic ulcer of skin 1.26 1.16–1.37
CCS = 158 Chronic kidney disease 1.23 1.12–1.34
CCS = 106 Cardiac dysrhythmias 1.21 1.07–1.36
CCS = 58 Other nutritional; endocrine; metabolic disorders 1.21 1.10–1.31
CCS = 129 Aspiration pneumonitis; food/vomitus 1.19 1.06–1.33
CCS = 122 Pneumonia 1.18 1.10–1.27
CCS = 653 Delirium; dementia 1.16 1.08–1.24
CCS = 117 Other circulatory disease 1.13 1.06–1.20
CCS = 108 Congestive heart failure; nonhypertensive 1.12 1.05–1.19
Chronicity of diagnosis dimension
CCS = 16 Liver cancer 5.83 1.97–17.20
CCS = 109 Acute cerebrovascular disease 2.93 1.42–6.05
CCS = 157 Acute renal failure 2.82 1.59–5.00
CCS = 127 COPD 1.99 1.32–3.01
CCS = 133 Other low resp. disease 1.51 1.29–1.76
CCS = 95 Other nervous disorders 1.45 1.32–1.60
CCS = 19 Bronchus; lung cancer 1.38 1.08–1.76
CCS = 49 Diabetes w/o complications 1.29 1.06–1.56
Non-POA diagnosis (CCS) dimension
CCS = 107 Cardiac arrest 3.82 3.13–4.67
CCS = 64 Other hematologic conditions 3.46 1.43–8.35
CCS = 162 Other bladder and urethra conditions 3.20 1.35–7.59
CCS = 149 Biliary tract disease 3.12 1.56–6.22
CCS = 114 Peripheral and visceral atherosclerosis 3.04 1.79–5.16
CCS = 257 Other aftercare 2.50 2.07–3.02
CCS = 259 Residual codes 2.46 2.26–2.68
CCS = 97 Peri-; endo-; myocarditis 2.30 1.58–3.34
CCS = 117 Other circulatory disease 1.69 1.46–1.96
CCS = 133 Other lower resp. disease 1.66 1.37–2.01
CCS = 3 Bacterial infection; unspecified site 1.51 1.13–2.02
CCS = 131 Respiratory failure; insufficiency; arrest 1.50 1.36–1.65
CCS = 238 Complications of surgical procedures or med. care 1.48 1.21–1.82
CCS = 2 Septicemia (except in labor) 1.37 1.17–1.61
CCS = 157 Acute and unspecified renal failure 1.34 1.20–1.49
CCS = 249 Shock 1.27 1.10–1.46
CCS = 95 Other nervous disorders 1.17 1.04–1.31
Medical procedure
CCS = 217 Other respiratory therapy (217) 3.84 2.30–6.41
CCS = 225 Conversion of cardiac rhythm (225) 3.64 3.23–4.10
CCS = 216 Respiratory intubation and mechanical ventilation 3.37 3.15–3.62
CCS = 49 Other OR heart procedures 1.70 1.35–2.12
CCS = 204 Swan-Ganz catheterization for monitoring 1.34 1.18–1.51
CCS = 54 Other vascular catheterization, not heart 1.33 1.23–1.44
CCS = 58 Hemodialysis (58) 1.29 1.16–1.44

Table 3.

Factors negatively associated with inpatient death

CCS code CCS description OR CI
Secondary diagnosis
CCS = 10 Immunization/screening .43 .34–.55
CCS = 93 Dizziness or vertigo .51 .32–.80
CCS = 127 COPD .51 .34–.77
CCS = 661 Substance disorders .51 .37–.72
CCS = 125 Acute bronchitis .53 .41–.67
CCS = 102 Nonspecific chest pain .54 .38–.75
CCS = 126 Other upper respiratory infection .55 .38–.81
CCS = 110 Precerebral artery stenosis .65 .54–.79
CCS = 160 Urinary tract calculus .69 .56–.86
CCS = 255 Admin/social admission .73 .63–.86
CCS = 252 Malaise and fatigue .74 .66–.83
CCS = 2617 Adverse effects of medical drugs .74 .66–.83
CCS = 99 Hypertension (HT) w. complicat.; secondary HT .75 .69–.82
CCS = 253 Allergic reactions .75 .69–.81
CCS = 95 Other nervous system disorders .79 .72–.87
CCS = 205 Spondylosis; disc disorders; other back problems .79 .71–.89
CCS = 3 Bacterial infection; unspecified site .79 .72–.88
CCS = 53 Disorders of lipid metabolism .80 .76–.84
CCS = 212 Other bone disease and musculoskel deformities .80 .69–.94
CCS = 98 Essential hypertension .81 .76–.87
CCS = 164 Hyperplasia of prostate .81 .74–.90
CCS = 663 Mental health and substance abuse screening .82 .77–.87
CCS = 163 Genitourinary symptoms and ill-defined cond. .82 .74–.91
CCS = 128 Asthma .84 .75–.93
CCS = 59 Deficiency and other anemia .85 .80–.91
CCS = 211 Other connective tissue disease .86 .78–.94
CCS = 50 Diabetes mellitus with complications .88 .82–.95
CCS = 203 Osteoarthritis .90 .84–.97
Chronicity of diagnosis dimension
CCS = 156 Nephritis; nephrosis .19 .05–.67
CCS = 114 Peripheral and visceral atherosclerosis .44 .32–.62
CCS = 259 Residual codes .45 .40–.50
CCS = 85 Coma; stupor; brain damage .50 .40–.62
CCS = 44 Unspecified neoplasms .57 .41–.80
CCS = 58 Other; endocrine; metabolic conditions .63 .57–.70
CCS = 83 Epilepsy; convulsions .70 .55–.90
CCS = 161 Other kidney/ureter .79 .62–.99
CCS = 131 Respiratory failure .81 .75–.87
CCS = 53 Lipid metabolism disorders .82 .72–.93
Non-POA diagnosis dimension
CCS = 200 Other skin disorders .28 .19–.66
CCS = 134 Other upper respiratory disorders .35 .21–.58
CCS = 199 Chronic ulcer of skin .57 .39–.83
CCS = 135 Intestinal infection .58 .42–.81
CCS = 145 Intestinal obstruction w/o hernia .62 .41–.83
CCS = 118 Phlebitis; embolism .65 .51–.84
CCS = 155 Other gastrointestinal disorder .69 .59–.80
CCS = 163 Genitourinary .70 .57–.87
CCS = 55 Fluid and electrolyte disorders .75 .69–.81
CCS = 108 Non-hypertensive CHF .75 .64–.88
CCS = 159 Urinary tract infections .75 .61–.92
CCS = 60 Acute posthemorrhagic anemia .76 .64–.92
CCS = 130 Pleurisy; pneumothorax; pulmonary collapse .78 .66–.91
Medical procedure
CCS = 172 Skin graft .14 .03–.60
CCS = 36 Lobectomy; pneumonectomy .15 .05–.47
CCS = 34 Tracheostomy .17 .13–.22
CCS = 48 Cardioverter/defibrillation .18 .13–.26
CCS = 156 Injections and aspirations .26 .09–.68
CCS = 228 Prophylactic vaccination .44 .26–.73
CCS = 111 Non-OR therapeutic procedure of the UT .47 .31–.73
CCS = 45 Percutaneous transluminal coronary angioplasty .48 .37–.62
CCS = 199 Electroencephalogram .51 .41–.64
CCS = 92 Other bowel diagnostic procedure .54 .40–.73
CCS = 76 Colonoscopy and biopsy .56 .36–.86
CCS = 98 Other non-OR gastrointest. therapeutic procedure .57 .43–.76
CCS = 47 Diagnost. cardiac catheteriz; coronary arteriogr. .58 .49–.69
CCS = 96 Other OR lower GI therapeutic procedures .66 .49–.89
CCS = 193 Diagnostic ultrasound of heart (echocardiogram) .66 .57–.77
CCS = 70 Upper gastrointestinal endoscopy; biopsy .67 .57–.79
CCS = 41 Other non-OR therapeut. proced. on resp. system .68 .54–.85
CCS = 223 Enteral and parenteral nutrition .72 .62–.84
CCS = 61 Other OR proc. on vessels oth. than the head and neck .76 .64–.91
CCS = 197 Other diagnostic ultrasound .77 .69–.87

For several diagnoses, the direction of the association was found to differ across the secondary diagnosis dimensions that this research developed. By examining a secondary diagnosis (a) simply as being present or not, (b) in terms of its chronicity, and (c) in terms of it being present on admission, the direction of its association with inpatient death can become different. Characteristically, the presence of CCS = 97 (peri-; endo-; myocarditis; cardiomyopathy) increases the likelihood for inpatient death when it is a hospital-developed condition (OR = 2.30, 1.58–3.34), but it is associated with a lower likelihood for death when it is studied in terms of its chronic nature, as a chronic disease (OR = .77, .62–.95). Similarly, while the presence CCS = 55 (fluid and electrolyte disorders) is associated with an increased likelihood for death, the direction of the association is negative when it is a hospital-acquired condition. The CCS = 114 (peripheral and visceral atherosclerosis) increases the likelihood of death if it is hospital-acquired, by three times (OR = 3.04, 1.79–5.16), but as a chronic condition, it is associated with a lower likelihood for hospital mortality (OR = .44, .32–.62) (Table 4).

Table 4.

Secondary diagnoses where the direction of association differs across the examined dimensions

Diagnosis (CCS) Is secondary diagnosis Is non-POA diagnosis Is chronic diagnosis
Peri-; endo-; myocarditis (97) 2.30 (1.58–3.34) .77 (.62–.95)
Nephritis/renal sclerosis (156) 6.70 (1.98–22.62) .19 (.05–.67)
Coma; stupor; brain damage (85) 4.46 (3.80–5.22) .50 (.40–.62)
Peripheral and visceral atheroscler. (114) 2.76 (1.97–3.85) 3.04 (1.79–5.16) .44 (.32–.62)
Respiratory failure; arrest (131) 2.48 (2.30–2.67) 1.50 (1.36–1.65) .81 (.75–.87)
Unspec Neopl/of uncertain behavior (44) 1.54 (1.21–1.95) .63 (.57–.70)
Intestinal obstruction w/o hernia (145) 1.51 (1.29–1.78) .62 (.41–.83)
Fluid and electrolyte disorders (55) 1.37 (1.29–1.45) .75 (.69–.81)
Chronic ulcer of skin (199) 1.26 (1.16–1.37) .57 (.39–.83)
Nutritional; endocrine; metabolic (58) 1.21 (1.10–1.31) .82 (.69–.96) .63 (.57–.70)
Congestive heart failure (108) 1.12 (1.05–1.19) .75 (.64–.88)
Bacterial infection (3) .79 (.72–.88) 1.51 (1.13–2.02)
Other nervous system disorders (95) .79 (.72–.87) 1.17 (1.04–1.31) 1.45 (1.32–1.60)
COPD (127) .51 (.34–.77) 1.99 (1.32–3.01)

Comparison with the Elixhauser Comorbidity Index

The 29 dichotomous comorbidity variables of the most recent Elixhauser Comorbidity Index version (2020.1) were inserted into the analysis dataset. The predictive power of the index was compared against the CCS-based collection of secondary diagnosis variables that the current research developed. The secondary diagnosis IVs were replaced with the 29 Elixhauser Index variables, while every other variable remained the same. We made this decision since the Elixhauser Index includes diagnoses independent of the principal diagnosis (chronic or preexisting). In that respect, the principal diagnosis (the reason for hospitalization) should remain in the dataset when examining the effect of comorbidities on outcomes: The effect of comorbidities on outcomes may differ depending on the principal diagnosis they are “combined” with.

The Nagelkerke R2 statistic was found to be .374 (compared to .499 with the proposed secondary diagnosis dimensions), the Sensitivitydeath was equal to .267 (compared to .306), and the PPVdeath was found to be .653 (compared to .655). While this is a small increase to the performance, especially considering the larger set of variables of our method, it is not a negligible one, especially in terms of the sensitivity of inpatient death detection.

The model that was developed with the Elixhauser Comorbidity Index contains much more principal diagnoses that were significantly associated with inpatient death. This was naturally expected because the Elixhauser Comorbidity Index was designed on the foundation of the independence between principal and secondary diagnoses. Finally, the direction of association for the 29 Elixhauser comorbidity categories when compared against the Elixhauser et al. original article [18] was found to differ in the current research for three of the twenty-nine Elixhauser Comorbidity Index categories: chronic lung disease, diabetes with complications, and psychoses. It should be noted that the scope of the Elixhauser Index is to serve as a robust collection of comorbidities independent of the principal diagnosis. The collection of diagnoses that our research presents is only compared against the Elixhauser Index to illustrate how our method can be a great alternative for inpatient-mortality-specific research.

Discussion

This is the first study to combine the new HCUP grouper files (for the 10th editions of ICD-CM and ICD-PCT), with medical claims data. The goal is to examine the predictive power of the clinical diagnosis dimensions that this study developed and to also recommend a critical collection of diagnosis and procedure predictors for inpatient mortality. CCS can be a workable way to gather information quickly regarding a healthcare topic [19] and has also been shown to be useful for improved predictions of mortality [20]. This research utilized the CCS system on ICD-10-CM data. While there are previous studies that examined the potential for CCS to be used in predicting hospital outcomes, they used the ICD-9-CM and ICD-9-PCT grouper versions.

Various comorbidity indexes have been developed to improve on measures of comorbidity in administrative databases and are often used as control variables in cross-sectional research. The Elixhauser Comorbidity Index labels secondary diagnoses as comorbidities only when these are disconnected from the principal diagnosis. To achieve this, it uses the DRGs to assess the independence of principal and secondary diagnoses. This is reflected in the comparison results of the present study: When the Elixhauser Comorbidity Index was used instead of the secondary diagnosis dimensions that this research developed, the principal diagnoses that were positively associated with hospital death were different and mostly consisted of malignancies. Illustratively, CCS = 20 (cancer; respiratory and intrathoracic), CCS = 31 (cancer of other genital organs), CCS = 24 (cancer of breast), CCS = 26 (cancer of cervix), and CCS = 41 (cancer, other principal) were the top principal diagnoses associated with an increased likelihood for inpatient mortality. When the secondary diagnosis dimensions were used instead, a majority of the aforementioned principal diagnosis were not found to be significant predictors of inpatient mortality. This can be explained, since, in acute care, death is oftentimes attributed to secondary ailments derivative of the principal diagnoses, and not from the principal diagnosis itself. The use of the secondary diagnosis dimensions that the present research developed was shown to contribute to a better prediction of inpatient mortality in comparison to the representation of secondary diagnoses with the Elixhauser Comorbidity Index. It appears that, while the Elixhauser Index includes a collection of comorbidities that are not related to the principal diagnosis, this data structure may not be optimal for the prediction of inpatient deaths among Medicare patients. The performance of the proposed multidimensional diagnosis collection, against the Elixhauser Comorbidity Index, was found to be slightly better, with a 7% increase to the sensitivity not being a negligible one.

Other comorbidity indexes, designed for long-term mortality, have been used in research to examine inpatient death. Unlike the Elixhauser Index, all these indexes were not originally designed for short-term outcomes in acute settings, D′ Hoore et al. [21] used the Charlson Index to study hospital death among patients with ischemic heart disease and found that the index was strongly associated with death. The Charlson Index has also been used to predict the cost of chronic disease in primary care [22]. Using study-specific weights with the Charlson variables has also been shown to improve the prediction of mortality [23]. Other approaches that the literature discusses include Cumulative Illness Rating Scale (CIRS), which addresses all relevant body systems without using specific diagnoses; the Index of Coexisting Disease (ICED) which has a two-dimensional structure, measuring disease severity and disability, which can be useful when mortality is the outcome of interest; and other disease-specific indexes like the Kaplan Index for diabetes research [24]. The main reason why the proposed set of diagnoses outperforms the Elixhauser Index is that the Elixhauser Index was not designed specifically for the study of inpatient mortality but serves as a collection of comorbidities that are independent of the cause for hospitalization. The additional information that our research feeds the model with was based on the capacity to predict in-hospital mortality with the three dimensions that were generated using the HCUP tool sets and POA information from the CMS LDS file.

Several diagnoses were found to be associated with a lower risk for hospital death (based on the expected risk). What this means in clinical terms is not that, for instance, asthma protects against death but that asthma is a lower risk factor for death than the expected risk for the overall inpatient population. Those associations can be explained case by case. For instance, congestive heart failure (CHF) is not a direct life-threatening condition for inpatient death as much as other heart diseases are, like acute myocardial infarction (AMI). CHF is characterized by chronicity and is very prevalent in elderly patients. When CHF develops more rapidly in-hospital, it can be life-threatening, and this is not the case for a chronic patient who has CHF for years and has been admitted to the hospital for a problem of a different nature. Besides, CHF is managed well with diuretics, beta-blockers, etc., and is not imminently life-threatening, unless it is of a late stage.

When hospital outcomes of care are studied, it is important to differentiate between principal and secondary diagnoses. Studies demonstrated the importance of this distinction by comparing hospital costs and length of stay, among other factors, between patients admitted with the principal and secondary diagnoses. Steward et al. showed that secondary diagnoses often led to longer hospital stays as well as higher hospital costs associated with their diagnoses. They also demonstrated that readmission rates may be higher for individuals with specific principal diagnoses [25].

The POA dimension of the secondary diagnoses is often available in administrative datasets and provides information on whether each diagnosis was acquired/recognized during the hospital stay or not. A non-POA diagnosis may be associated with unique treatment challenges, especially when it is derivative from the principal diagnosis. In some other cases, though, it can be easier to treat a hospital-acquired diagnosis due to a timelier response to a newfound problem. Hospital-acquired conditions (HACs) are associated with negative outcomes of care and many studies have examined predictors of HACs [26]. Glance et al. found that mortality, cost, and length of stay were significantly higher among trauma patients who had developed hospital-acquired infections [27]. According to IBM-Watson Health [28], HACs can increase mortality risk per patient by 72.32%. As in the current study, Lagu et al. [29] also used POA codes to identify other acute conditions that are of concern but that are not recognized in the Elixhauser Comorbidity Index. Other approaches to study comorbidities were proposed in the literature, such as the Romano Index [30].

The current research utilized the chronic condition indicators of HCUP to recognize secondary diagnoses of a chronic nature. CCI has been used in other studies, like in [31], to understand the prevalence of chronic conditions and medical expenditures of the elderly for healthcare planning development of chronic conditions, to study child cancer complications [32], medical morbidity narcolepsy, and more [33]. Some of the previously mentioned studies also adopted CCI and CCS by the AHRQ to determine chronic condition diagnostic codes and classify the diseases.

The prediction of hospital mortality has been a popular research topic [34, 35]. While the statistical approaches may vary, many of the studies used multivariate logistic regression and the development of prediction rules. Most studies focus on specific conditions, though. For instance, among cardiology patients, attributes contributing to inpatient mortality were found to be history of congestive heart failure and the time between the onset of a cardiac event and starting chest compressions [36]. Claxton found that age, neurological lever, and Glasgow Coma Scale can be used independently to predict mortality in patients who suffer traumatic cervical spine [37]. For patients who have very extended stays in the ICU, a prolonged requirement for life support therapies and a limited number of preexisting comorbidities both are predictors of increased hospital mortality [38] while mean platelet volumes and platelet distribution width both have been shown to contribute to the prediction of mortality in ICU patients [39]. For patients following operative management of hip fractures, the list of predictors of mortality includes male gender, admission from a long-term facility, age greater than 90 years, living at home with support, and the presence of a postoperative complication [40]. The present research followed a non-disease-specific approach to find the predictors of all-cause death. Existing studies, including the aforementioned ones, follow more conventional research designs and statistical approaches, without the prediction being their objective but, instead, the knowledge about statistical associations with mortality. It is finally worth mentioning that, in the present study, when examining comorbidities with the NB classifier, the comorbidity interactions are ignored. In our work, the sensitivity to detect hospital death was higher with NB, despite this. One reasonable explanation is that the outcome of death may have predictors that act as predominant and exist as such, regardless of other interactions with coexisting conditions.

Limitations

This study was conducted with the use of CMS claims data; therefore, results should be interpreted with caution for non-Medicare acute cases. Besides, the fact that the present study focuses on the CCS classification may be associated with an inherent limitation, which is the amount of disease specificity that may be lost because of the transition from ICD to CCS. The study did not compare the model performance of an ICD versus CCS representation of the dimensions. Modeling more than seventy-thousand different ICD-10-CM codes would lead to multicollinearity and overfitting issues. The researchers, though, would like to encourage future research efforts to focus on estimating how much of the predictive power is compromised when CCS is used instead of the original ICD codes. Finally, the authors believe that the model performance of the present study can be better if additional features were available, such as laboratory examination results, postoperative complication rates, and patient consciousness level. This research intends to set a paradigm for medical claims data, though, and, these details are not typically present in such datasets. Another aspect related to inpatient mortality is the increasing utilization of non-acute settings (such as hospices) for patients with end-stage disease. In that respect, the dataset that this research used may be underestimating these deaths. This is an inherent limitation of hospital mortality studies. The present research therefore does not seek to predict whether a patient will die or not but whether a patient will be discharged from the hospital with a “died” status. It is also worth mentioning that the only demographics available in the CMS LDS dataset that the study used is gender, age, and ethnicity. Of these three demographic variables, only age was found to be associated with inpatient mortality in a statistically significant way. Finally, while there exist other approaches to study comorbidities, such as the aforementioned Romano Index, an adaptation of Charleston, these approaches have not been updated to support the ICD-10-CM that this study examines; and therefore, this study could not examine their predictive power against our method.

Conclusion

When using medical claims data for inpatient outcomes research, the combined use of HCUP tools with other medical claims metadata (POA indicator) can improve the prediction of inpatient death among Medicare patients. Also, this combined use provides improved predictions when compared against the well-known Elixhauser Comorbidity Index. The collection of critical dimensions of diagnoses (principal, secondary, hospital-acquired, chronic) and medical procedures that this study recommends may be used in future research efforts for a better understanding of drivers of inpatient mortality. This is especially important since this is the first study that uses the newly published grouping files of CCS and CCI with the 10th edition of ICD-CM. The findings of this study can contribute to hospitals having access to updated inpatient mortality risk information. This information can make it easier to prioritize proactive care and rank high-risk admissions for improved inpatient care management. The work also provides a foundation to develop a minimum set of inpatient mortality diagnosis predictors for future studies of mortality that utilize medical claim datasets.

Declarations

Conflict of Interest

The authors have no competing interests.

Footnotes

Publisher’s Note

Springer Nature remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.

Contributor Information

Dimitrios Zikos, Email: zikos1d@cmich.edu.

Aashara Shrestha, Email: aashara.shrestha@mavs.uta.edu.

Leonidas Fegaras, Email: fegaras@cse.uta.edu.

References

  • 1.Taylor A, Pare J, Venkatesh A, et al. Prediction of hospital mortality in emergency department patients with sepsis: a local big data-driven, machine learning approach. Acad Emerg Med. 2016;23(3):269–278. doi: 10.1111/acem.12876. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 2.Khojandi A, Tansakul V, Li X, Koszalinski RS, Paiva W. Prediction of sepsis and hospital mortality using electronic health records. Methods Inf Med. 2018;57(4):185–193. doi: 10.3414/ME18-01-0014. [DOI] [PubMed] [Google Scholar]
  • 3.Awad A, Bader-El-Den M, McNicholas J, et al. Early hospital mortality prediction of intensive care unit patients using an ensemble learning approach. Int J Med Inform. 2017;108:185–195. doi: 10.1016/j.ijmedinf.2017.10.002. [DOI] [PubMed] [Google Scholar]
  • 4.Awad A, Bader-El-Den M, James McNicholas J. Patient length of stay and mortality prediction: a survey. Health Serv Manag Res. 2017;30(2):105–120. doi: 10.1177/0951484817696212. [DOI] [PubMed] [Google Scholar]
  • 5.Partington A, Chew DP, Ben-Tovim D, Horsfall M, Hakendorf P, Karnon J. Screening for important unwarranted variation in clinical practice: a triple-test of processes of care, costs, and patient outcomes. Aust Health Rev. 2017;41(1):104–110. doi: 10.1071/AH15101. [DOI] [PubMed] [Google Scholar]
  • 6.Krautz C, Nimptsch U, Weber G, et al. Effect of hospital volume on hospital morbidity and mortality following pancreatic surgery in Germany. Ann Surg. 2018;267(3):411–417. doi: 10.1097/SLA.0000000000002248. [DOI] [PubMed] [Google Scholar]
  • 7.Amato L, Fusco D, Acampora A et al (2017) Volume and health outcomes: evidence from systematic reviews and from evaluation of Italian hospital data. Epidemiol Prev 41(5–6 (Suppl 2)):1–128 [DOI] [PubMed]
  • 8.Elsebaey MA, Elashry H, Elbedewy TA, Elhadidy AA, Esheba NE, Ezat S, Negm MS, Abo-Amer YEE, Abgeegy ME, Elsergany HF, Mansour L, Abd-Elsalam S. Predictors of hospital mortality in a cohort of elderly Egyptian patients with acute upper gastrointestinal bleeding. Medicine (Baltimore) 2018;97(16):e0403. doi: 10.1097/MD.0000000000010403. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 9.Özgür Doğan N, Akıncı E, Gümüş H, et al. Predictors of inhospital mortality in geriatric patients presenting to the emergency department with ischemic stroke. Clin Appl Thromb Hemost. 2016;22(3):280–284. doi: 10.1177/1076029614550820. [DOI] [PubMed] [Google Scholar]
  • 10.Morsy KH, Ghaliony MA, Mohammed HS. Outcomes and predictors of hospital mortality among cirrhotic patients with non-variceal upper gastrointestinal bleeding in upper Egypt. Turk J Gastroenterol. 2014;25(6):707–713. doi: 10.5152/tjg.2014.6710. [DOI] [PubMed] [Google Scholar]
  • 11.Burke R, Jones C, Hosokawa P, et al. Influence of nonindex hospital readmission on length of stay and mortality. Med Care. 2018;56(1):85–90. doi: 10.1097/MLR.0000000000000829. [DOI] [PubMed] [Google Scholar]
  • 12.US Tools & Software Page. HCUP. https://www.hcup-us.ahrq.gov/toolssoftware/ccs/ccs.jsp Accessed 7 Feb 2020
  • 13.Chronic Condition Indicator (CCI) for ICD-10-CM (Beta Version). https://www.hcup-us.ahrq.gov/toolssoftware/chronic_icd10/chronic_icd10.jsp. Accessed 7 Feb 2020
  • 14.Fowler B, Rajendiran M, Schroeder T et al (2017) Predicting patient revisits at the University of Virginia health system emergency department. In Systems and Information Engineering Design, SIEDS, IEEE Symposium
  • 15.Tabak Y, Sun X, Nunez C, et al. Using electronic health record data to develop hospital mortality predictive model: acute laboratory risk of mortality score (alarms) J Am Med Inform Assoc. 2014;21(3):455–463. doi: 10.1136/amiajnl-2013-001790. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 16.Concept: Elixhauser Comorbidity Index. http://mchpappserv.cpe.umanitoba.ca/viewConcept.php?printer=Y&conceptID=1436#a_references. Accessed 7 Feb 2020
  • 17.Sessler DI, Sigl JC, Manberg PJ, Kelley SD, Schubert A, Chamoun NG. Broadly applicable risk stratification system for predicting duration of hospitalization and mortality. Anesthesiology. 2010;113:1026–1037. doi: 10.1097/ALN.0b013e3181f79a8d. [DOI] [PubMed] [Google Scholar]
  • 18.Elixhauser A, Steiner C, Harris DR, et al. Comorbidity measures for use with administrative data. Med Care. 1998;1:8–27. doi: 10.1097/00005650-199801000-00004. [DOI] [PubMed] [Google Scholar]
  • 19.Fogerty MD, Abumrad NN, Nanney L, Arbogast PG, Poulose B, Barbul A. Risk factors for pressure ulcers in acute care hospitals. Wound Repair Regen. 2008;16(1):11–18. doi: 10.1111/j.1524-475X.2007.00327.x. [DOI] [PubMed] [Google Scholar]
  • 20.Ash AS, Posner MA, Speckman J, Franco S, Yacht AC, Bramwell L. Using claims data to examine mortality trends following hospitalization for heart attack in Medicare. Health Serv Res. 2003;38(5):1253–1262(10). doi: 10.1111/1475-6773.00175. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 21.D'Hoore W, Bouckaert A, Tilquin C. Practical considerations on the use of the Charlson comorbidity index with administrative databases. J Clin Epidemiol. 1996;49(12):1429–1433. doi: 10.1016/S0895-4356(96)00271-5. [DOI] [PubMed] [Google Scholar]
  • 22.Charlson ME, Charlson RE, Peterson JC, Marinopoulos SS, Briggs WM, Hollenberg JP. The Charlson comorbidity index is adapted to predict costs of chronic disease in primary care patients. J Clin Epidemiol. 2008;61(12):1234–1240. doi: 10.1016/j.jclinepi.2008.01.006. [DOI] [PubMed] [Google Scholar]
  • 23.Ghali WA, Hall RE, Rosen AK, Ash AS, Moskowitz MA. Searching for an improved clinical comorbidity index for use with ICD-9-CM administrative data. J Clin Epidemiol. 1996;49(3):273–278. doi: 10.1016/0895-4356(95)00564-1. [DOI] [PubMed] [Google Scholar]
  • 24.De Groot V, Beckerman H, Lankhorst GJ, Bouter LM. How to measure comorbidity: a critical review of available methods. J Clin Epidemiol. 2003;56(3):221–229. doi: 10.1016/S0895-4356(02)00585-1. [DOI] [PubMed] [Google Scholar]
  • 25.Stewart D, Wang L. Hospital costs, length of stay and readmission rates for C. difficile colitis: comparing outcomes between CDC as the principal and secondary admission diagnosis. Gastroenterology. 2011;140(5):S-1013. doi: 10.1016/S0016-5085(11)64206-6. [DOI] [Google Scholar]
  • 26.Di Capua J, Somani S, Kim J, et al. Hospital-acquired conditions in adult spinal deformity surgery: predictors for hospital-acquired conditions and other 30-day postoperative outcomes. SPINE. 2017;42(8):595–602. doi: 10.1097/BRS.0000000000001840. [DOI] [PubMed] [Google Scholar]
  • 27.Glance L, Stone P, Mukamel D, et al. Increases in mortality, length of stay, and cost associated with hospital-acquired infections in trauma patients. Arch Surg. 2011;146(7):794–801. doi: 10.1001/archsurg.2011.41. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 28.Research brief: Hospital-acquired conditions lead to avoidable cost and excess deaths. Watson Health Perspectives 2019. https://www.ibm.com/blogs/watson-health/research-brief-hospital-acquired-conditions-lead-to-avoidable-cost-and-excess-deaths/. Accessed 7 Fe 2020
  • 29.Lagu T, Pekow PS, Stefan MS, Shieh MS, Pack QR, Kashef MA, Atreya AR, Valania G, Slawsky MT, Lindenauer PK. Derivation and validation of an in-hospital mortality prediction model suitable for profiling hospital performance in heart failure. J Am Heart Assoc. 2018;7(4):e005256. doi: 10.1161/JAHA.116.005256. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 30.Gagne JJ, Glynn RJ, Avorn J, Levin R, Schneeweiss S. A combined comorbidity score predicted mortality in elderly patients better than existing scores. J Clin Epidemiol. 2011;64(7):749–759. doi: 10.1016/j.jclinepi.2010.10.004. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 31.Chi M-j, Lee C-y, Wu S-c. The prevalence of chronic conditions and medical expenditures of the elderly by chronic condition indicator (CCI) Arch Gerontol Geriatr. 2011;52(3):284–289. doi: 10.1016/j.archger.2010.04.017. [DOI] [PubMed] [Google Scholar]
  • 32.Lekshminarayanan A, Bhatt P, Gandhi V, et al. National trends in hospitalization for fever and neutropenia in children with cancer, 2007–2014. J Pediatr. 2018;202:231–237.e3. doi: 10.1016/j.jpeds.2018.06.056. [DOI] [PubMed] [Google Scholar]
  • 33.Black J, Reaven F, Mcgaughey O, et al. Medical comorbidity in narcolepsy: findings from the Burden of Narcolepsy Disease (BOND) study. Sleep Med. 2017;33:13–18. doi: 10.1016/j.sleep.2016.04.004. [DOI] [PubMed] [Google Scholar]
  • 34.Sakhnini A, Saliba W, Schwartz N et al (2017) The derivation and validation of a simple model for predicting in-hospital mortality of acutely admitted patients to internal medicine wards. Medicine 96(25) [DOI] [PMC free article] [PubMed]
  • 35.Brown LM, Calfee CS, Matthay MA, Brower RG, Thompson BT, Checkley W, National Institutes of Health Acute Respiratory Distress Syndrome Network Investigators A simple classification model for hospital mortality in patients with acute lung injury managed with lung protective ventilation. Crit Care Med. 2011;39(12):2645–2651. doi: 10.1097/CCM.0b013e3182266779. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 36.Hallstrom AP, Cobb LA, Swain M, et al. Predictors of hospital mortality after out-of-hospital cardiopulmonary resuscitation. Crit Care Med. 1985;13(11):927–929. doi: 10.1097/00003246-198511000-00019. [DOI] [PubMed] [Google Scholar]
  • 37.Claxton AR, Wong DT, Chung F, Fehlings MG. Predictors of hospital mortality and mechanical ventilation in patients with cervical spinal cord injury. Can J Anaesth. 1998;45(2):144–149. doi: 10.1007/BF03013253. [DOI] [PubMed] [Google Scholar]
  • 38.Friedrich JO, Wilson G, Chant C. Long-term outcomes and clinical predictors of hospital mortality in very long stay intensive care unit patients: a cohort study. Crit Care. 2006;10(2):R59. doi: 10.1186/cc4888. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 39.Zhang Z, Xu X, Ni H, Deng H. Platelet indices are novel predictors of hospital mortality in intensive care unit patients. J Crit Care. 2014;29(5):885–8e1. doi: 10.1016/j.jcrc.2014.06.015. [DOI] [PubMed] [Google Scholar]
  • 40.Bhandari M, Koo H, Saunders L, Shaughnessy SG, Dunlop RB, Schemitsch EH. Predictors of hospital mortality following operative management of hip fractures. Int J Surg Investig. 1999;1(4):319–326. [PubMed] [Google Scholar]

Articles from Journal of Healthcare Informatics Research are provided here courtesy of Springer

RESOURCES