The use of cardiovascular health services is greater among patients with depressive symptoms than among patients without. However, the extent to which such associations between depressive symptoms and health service utilization are attributable to variations in comorbidity and prognostic disease severity is unknown. This paper explores the relationship between depressive symptoms, health service cardiovascular consumption, and prognosis following acute myocardial infarction (AMI).
The study design was a prospective cohort study with follow-up telephone interviews of 1,941 patients 30 days following AMI discharged from 53 hospitals across Ontario, Canada between December 1999 and February, 2003. Outcome measures were post discharge use of cardiac and non-cardiac health care services. The service utilization outcomes were adjusted for age, sex, income, comorbidity, two validated measures of prognosis (cardiac functional capacity and risk adjustment severity index), cardiac procedures (CABG or PTCA) and drugs prescribed at discharge.
Depressive symptoms were associated with a 24% (Adjusted RR:1.24; 95% CI:1.19–1.30, P < 0.001), 9% (Adjusted RR:1.09; 95% CI:1.02–1.16, P = 0.007) and 43% (Adjusted RR: 1.43; 95% CI:1.34–1.52, P < 0.001) increase in total, cardiac, and non-cardiac hospitalization days post-AMI respectively, after adjusting for baseline patient and hospital characteristics. Depressive-associated increases in cardiac health service consumption were significantly more pronounced among patients of lower than higher cardiac risk severity. Depressive symptoms were not associated with increased mortality after adjusting for baseline patient characteristics.
Depressive symptoms are associated with significantly higher cardiac and non-cardiac health service consumption following AMI despite adjustments for comorbidity and prognostic severity. The disproportionately higher cardiac health service consumption among lower-risk AMI depressive patients may suggest that health seeking behaviors are mediated by psychosocial factors more so than by objective measures of cardiovascular risk or necessity.
Available evidence has demonstrated that health service consumption is higher among patients with depression than those without. In ambulatory care settings, depression is associated with a 50% increase in general medical service use, even after adjusting for age, sex and chronic medical comorbidities[1, 2]. Similar depression-related service consumption patterns have been described among cohorts with cardiovascular disease[3, 4].
Some authors advocate that increased health service consumption among cardiac-specific patients with depression is appropriate and concordant with their underlying cardiovascular prognosis. However, others contend that depressed patients seek more health care services regardless of illness severity. Evidence from utilization patterns of depressed patients in primary care settings suggest that depressed patients use more health care services than non-depressed patients regardless of medical illness severity . Few studies have quantified the relationship between depressive symptoms, illness severity, and health service consumption.
Accordingly, the objective of our study was to evaluate the impact of depressive symptoms on health service consumption and cardiovascular prognosis following AMI. AMI serves as a useful test case because the natural history of the disease has been well-described and validated measures of cardiac prognostic risk severity exist. Yet, unexplained variations in health service consumption exist across patient populations[9, 10]; similar health service consumption variations may be explained by psychosocial factors. Because Canada's federal-provincial Medicare plan covers medically necessary services based on need rather than affordability, differences in health service consumption are more likely to reflect differences in health service behaviors than in a system where services are provided based on an ability to pay . We hypothesized that health service consumption following AMI would be increased among patients with depressive symptoms as compared to those without and would be independent of comorbidity and cardiac illness severity.
Health system context
Canada's universal health insurance system provides comprehensive coverage for most medical and hospital services without user fees at point of service. Under such provisions, patients are entitled to equitable access to health care services based on medical need, regardless of age, financial status, or financial circumstances.
Data source and study sample
This study is a sub-study of the Socio-Economic and Acute Myocardial Infarction Study (SESAMI) study, a prospective observational study of patients who were hospitalized for AMI throughout Ontario, Canada. Patients were included if they were English-speaking and if 2 of 3 AMI criteria were met: presence of symptoms, abnormal electrocardiographic findings, or elevated serum levels of cardiac enzymes. Patients were excluded if they were younger than 19 years of age or older than 101 years of age, lacking a valid health card number issued by the province of Ontario, and those who were transferred to the recruiting hospital. Eligibility for the study required completion of a self-administered baseline survey; patients who died within 24 hours of admission, who had very severe illness, who had language barriers, or who underwent early discharge or transfer were therefore ineligible. Data came from four sources: 1) a baseline survey; 2) chart abstraction from index AMI; 3) a one-month follow-up phone survey; and 4) linked health administrative data. From 2829 patients with successfully abstracted index AMI admissions and linked health administrative data, 888 (31%) subjects did not complete the one-month follow-up survey either because of death prior to the survey (N = 73; 2%) or a refusal to participate (N = 815; 29%). A total of 1941 (69%) patients remained available for analysis. The SESAMI cohort has been described in detail elsewhere. The Sunnybrook Health Sciences Centre Review Committee approved this study and all subjects gave informed consent to participate.
Depressive symptom measures
The SESAMI survey consisted of psychometric questions that explored various domains related to depression, including low mood, loss of interest, sleep disturbance, reduced appetite/wt loss, agitation/slowing, low self-esteem/guilt, suicidal thoughts, reduced energy level, loss of concentration (Table 1). The SESAMI surveys were telephone administered by standardized trained health care personnel (nurses).
BCDRS* items (included and missing) and replacement items from SESAMI survey
I am losing weight.
Loss of appetite/weight loss
I have dropped many of my interests and activities.
Loss of interest
It must be obvious that I am disturbed and agitated.
I am miserable or often feel like crying.
I often wish I were dead.
I feel in good spirits.
I still enjoy my meals.
Loss of appetite.
I get hardly anything done lately.
I am exhausted much of the time.
My sleep is restless and disturbed.
I can concentrate easily when reading the papers.
I feel worthless and ashamed about myself.
During the past week how much of the time have you had trouble sleeping for example, having trouble falling asleep or waking up too early and unable to get back to sleep?*
*The BCDRS and SF-12 items were dichotomous (yes/no). The GUSTO trial items had 4 options from None of the time, some of the time (1–2 days/wk), some of the time (3–4 days/wk), and All/most of the time (5 or more days/wk). The GUSTO items were dichotomized around the median of 3 or more days/wk.
Nine of twelve questions were directly abstracted from the Brief Carroll Depression Rating Scale (BCDRS). These nine questions served as our primary determinant of depressive symptoms. The original 12-item BCDRS is a depression rating scale which has been validated among hospitalized mentally ill populations, and has a sensitivity of 92% and a specificity of 89% using a cut-off scale of 6 .
While a score of 6 or more of the original 12-item BCDRS has been used to define depression, affirmative responses to 5 or more of the 9 administered BCDRS items were used to define patients as having "depressive symptoms" for the purposes of our study. A score of 5 rather than 6 was used because it corresponded most closely with the median score of 6, and because five or more depressive constructs are required to fulfill DSM-IV criteria for depression, and hence is concordant with the diagnostic criterion threshold from DSM-IV .
The three questions comprising the 12-item BCDRS not included in the SESAMI survey, related to sleep disturbance, concentration, and self-esteem, and were as follows:: "my sleep is restless and disturbed"; "I can concentrate easily when reading the paper"; and "I feel worthless and ashamed about myself". However, these missing questions were replaced with the following: "During the past week, how much time have you had trouble sleeping for example, having trouble falling asleep or waking up too early and unable to get back to sleep"; "During the past week, how much of the time have you had trouble concentrating or keeping your mind on what you're doing?"; and "You are a burden on others" (Table 1). These three items were abstracted from two data sources: The first two replacement items originated from a depression measure incorporated within the Global Utilization of Streptokinase and t-PA for Occluded Coronary Arteries (GUSTO) trial quality of life substudy , whose design served as the foundation for the SESAMI. The remaining replacement item originated from the SF-12. For scoring purposes, responses related to the first 2 replacement questions were dichotomized around the median (3+ days per week vs. < 2 days per week). The last replacement question elicited a binary response (Table 1). These three additional replacement questions were analyzed separately from the 9-item BCDRS and reported within the sensitivity analysis section below.
Demographic factors such as age, sex, and income tertile were acquired from the baseline survey and were based on patient self-report.
Cardiovascular risk severity
Two validated measures of cardiovascular risk-severity were used in this study:
The first measure was the Global Registry of Acute Coronary Events (GRACE) prognostic index. The GRACE prognostic index provides a score that reflects the probability of dying within 6 months post-AMI based on age, development (or history) of heart failure, peripheral vascular disease, systolic blood pressure, Killip class, initial serum creatinine concentration, elevated initial cardiac markers, cardiac arrest on admission, and ST segment deviation. The GRACE prognostic index has been validated among SESAMI patients. In addition to the GRACE prognostic index, we examined other cardiovascular risk factors, which included diabetes, hypertension, hyperlipidemia, and current or former cigarette use. Smoking history was ascertained by questionnaire. Major cardiovascular risk factors were determined by reviewing diagnostic fields in computerized hospital discharge abstracts from April 1, 1988 to the index hospitalization date using all primary and secondary ICD-9 and ICD-10 (where applicable) discharge codes. Agreement between self-reported risk factors and chart audit range was between 73% (hyperlipidemia) and 95% (diabetes) .
The second measure was the Duke Activity Status Index (DASI), administered to all participants. The DASI is a self-report measure validated to determine functional capacity which correlates well with peak oxygen uptake, one of the most important single predictors of long-term cardiovascular survival across populations.
Preexisting noncardiovascular comorbid conditions
Noncardiovascular risk factors consisted of all co-morbid diseases that were captured through primary and secondary diagnostic fields of hospital discharge abstracts (Canadian Institute for Health Information) from 1 April 1988 to the presenting hospitalization. This method has been used and demonstrated to increase the prevalence of chronic conditions, which historically are known to be under-coded using single data sources alone[19, 20]. Furthermore, supplementing clinical data sources with longer retrospective ascertainment of comorbidities using administrative data has been shown to improve accuracy . Non-cardiovascular conditions were categorized as cancer and as diseases of the central nervous system, endocrine system, hematology system, musculoskeletal system, respiratory system, gastrointestinal system, and genitourinary system. We categorized diabetes, secondary hypertension, and hyperlipidemia as cardiovascular risk factors, not as diseases of the endocrine system. Available evidence has demonstrated that the number of non-cardiac comorbidities have independent prognostic significance in patients with cardiovascular illness. For the purposes of our study, non-cardiac comorbidities were analyzed as a count variable (0, 1, 2 or 3 or more). However, a re-analysis of our data in which we incorporated both the count, and the type of non-cardiac comorbidity did not alter our results.
Early peri-infarction procedure and medication use
All of our outcomes could be influenced by whether or not a patient has received revascularization by angioplasty or coronary bypass surgery. All revascularization procedures occurring within 30 days of discharge from the index AMI hospitalization were recorded within the Ontario Health Insurance Program database. In addition, we examined the influence of cardiovascular medication (Beta-blockers, statins, ACE inhibitors, and nitrates) prescribed at discharge from index admission as acquired from chart abstraction.
Our primary outcomes included cumulative outpatient physician and emergency room visits, the number and duration of recurrent hospitalizations, as well as total hospitalizations and ambulatory physician visits over the 18 months following index AMI hospitalization discharge. These outcomes were chosen because they reflect health care consumption measures that can be accurately measured in the linked administrative health data sets. Secondary outcomes included mortality, recurrent AMI, as well as time to first re-admission for cardiac-specific readmissions as general measures of prognosis. We examined recurrent AMI hospitalizations separately from other cause-specific admissions because recurrent AMI represents a deleterious prognostic outcome indicator. Moreover, unlike our other hospitalizations which are based on more discretionary criteria, recurrent AMI admissions are based on more standardized, objective clinical, laboratory, and ECG parameters. However, a re-analysis in which recurrent AMI was categorized together with the other health service consumption variables did not alter our results. Recurrent AMI was defined using the most-responsible diagnosis field of ICD-9 and ICD-10. Cardiac specific re-admissions were ascertained using sets of the CIHI most-responsible diagnosis codes (AMI: ICD-9 410, 412, 4141; ICD-10 I21, I22, and I2382; angina: ICD-9 411, 413, 4140, and 4142–4149; ICD-10 I20, I241, I251, I252, I253, and I258; CHF: ICD-9 428, 415, 4254, 4298; ICD-10 I50, I255, I420, I429) that a previous study has shown have modest sensitivity, but high specificity.
The Mantel-Haenszel test for trend was used for categorical data and t-tests (or nonparametric tests where relevant) were used for continuous data to detect unadjusted differences in baseline characteristics. We estimated Poisson regression models for rates of service utilization, as well as Cox proportional hazard models for mortality, recurrent AMI, and time to first angina hospitalization, adjusting for age, sex, income, cardiac risk factors, total medical comorbidities, prognostic index (GRACE score and DASI), drugs at discharge, and peri-infarction procedures using non-parsimonious modeling. Formal diagnostic testing revealed no evidence of multi-collinearity in any of our statistical models. We tested for violations of the proportionality assumption in all proportional hazard model specifications. Finally, for the health service utilization multivariable models, we used generalized estimating equations (GEE) to adjust for hospital-level variations in patient care.
All analyses were performed using SAS statistical software, version 9.1 (SAS Institute, Cary, NC).
We conducted a number of sensitivity and sub-group analyses. First, we examined the relationship between the 3 replacement questions and health service utilization. Second, we examined the use of different cut-off scores to define "depressive symptoms" for both the 9-item BCDRS and the 3 depressive-symptom replacement items. Finally, multiple imputation was used to impute depression measures for the 888 missing depression values due to non-response to test whether our outcomes were affected by systematic differences between survey responders and non-responders. Variables used to model the missing data included demographic variables (age, sex, SES), cardiac risk factors and illness severity (GRACE prognostic index and DASI), revascularization procedures, drugs prescribed at discharge, and the 9-item depression scale. There was no difference between aggregated results from 5 and 10 imputed data sets; results from 5 imputed data sets are reported. The missing depression measures were imputed using PROC MI and the results from the multiple, imputed data sets were aggregated using PROC MIAnalyze in SAS version 9.1 (SAS Institute, Cary, NC).
The 888 (31%) patients who did not respond to the one month follow-up survey were similar to the 1941 subjects in terms of gender, cardiac risk factors, likelihood of receiving revascularization procedures within 30 days of discharge, and the likelihood of receiving ACE inhibitors, Beta blockers, and nitrates upon discharge. However, the sample of 888 survey non-respondents were older (mean (SD) age of respondents 66.3 (13.7) years vs. 62.4 (12.8) years; P < 0.001), more likely to have 3 or more non-cardiac medical comorbidities (55.7% vs. 47.2%; P < 0.001), less likely to receive statins upon discharge (48.7% vs. 54.9%; P = 0.002), and had a higher GRACE score (predictive of 6 month mortality)(4.1 vs. 3.2; P < 0.001) than the 1941 survey respondents who consented and completed the 1 month post-myocardial infarction evaluation.
Among the 1941 subjects included in this study, the median age was 64 years (range, 26 to 96 years). 575 (29.6%) were women. Table 2 illustrates that the baseline characteristics of patients reporting five or more depressive symptoms differed from those reporting fewer depressive symptoms. Specifically, patients with depressive symptoms were more likely to be female, were less affluent, and were more likely to have diabetes, hypercholesterolemia, and non-cardiac comorbidities. There were no significant differences in baseline cardiovascular prognosis (GRACE scores 109.5 vs. 113.0, p = 0.22), but patients with depressive symptoms had poorer cardiovascular functional status (DASI score 11.2 vs. 19.6, p < 0.001; lower score indicates worse peak oxygen uptake)(Table 2).
(n = 494)
(n = 1447)
Age, y -- %
Male Sex -- %
Income, Canadian $ -- %
Intermediate ($30,000 – $59,999)
Coronary Risk Factors -- %
Non-cardiac comorbidities -- %
3 or more
Prognostic Indicators -- mean (SD)
GRACE 6-month prognostic index score⌷
Processes of Care -- %
Percutaneous transluminal coronary angiography
Coronary angioplasty bypass grafting
*The depression measure is a depression scale containing 9 items from the Brief Carroll Depression Scale (BCDS)(cut-off score of 5).
⌷Abbreviation: GRACE: Global Registry of Acute Coronary Events scale.
§Abbreviation: DASI: Duke Activity Status Index
Health service consumption
Total number of hospitalizations, total number of hospitalization days, length of hospital stays, and post-AMI ambulatory service use were greater for patients with depressive symptoms (Table 3).
Health service consumption in depressed and non-depressed post-AMI patients.
Service Consumption Variable
Hospitalization -- mean (SD)
Total hospitalization days⌷
Total cardiac hospitalization days⌷
Total non-cardiac hospitalization days⌷
Total number of hospitalizations
Total number of cardiac hospitalizations
Total number of non-cardiac hospitalizations
Ambulatory service consumption -- mean (SD)
General internist visits
Family doctor visits
Emergency department visits
*The depression measure is a depression scale containing 9 items from the Brief Carroll Depression Scale (BCDS)(cut-off score of 5).
⌷Hospitalization days are a count of total days in hospital over the 18-month follow-up period and can accumulate from multiple hospitalizations.
After adjustment for age, sex, income, risk factors, medical comorbidity, prognosis (GRACE score), drugs at discharge, 30-day procedure use (percutaneous coronary interventions and/or coronary artery bypass surgery), and symptom burden (DASI), depressive symptoms remained an independent predictor of most service consumption measures, with a 24% (Adjusted RR:1.24, 95% CI:1.19–1.30, P < 0.001) increase in all cause re-hospitalizations, a 9% (Adjusted RR:1.09; 95% CI:1.02–1.16, P = 0.007) increase in cardiac-related hospitalizations and a 43% (Adjusted RR:1.43; 95% CI:1.34–1.52, P < 0.001) increase in non-cardiac hospitalizations visits following AMI discharge (Figure 1). Depressive symptoms were associated with increases in cardiology, internal medicine and family practice visits after adjustment for baseline variables (Figure 1).
Cardiac-specific re-admissions were comprised mostly of angina and CHF hospitalizations. Depressed patients were substantially more likely to be admitted for angina in the 18 months post-AMI than non-depressed patients (HR 1.75; 95% C.I. 1.44 – 2.14), even when the DASI is included in the model (HR 1.41; 95% C.I. 1.14–1.75). However, after adjusting for emergency-room visits, depression was no longer a significant predictor of hospital readmissions.
To evaluate whether depressive-associated increases in health service consumption were consistent across cardiac illness risk severity levels, subgroup analyses were performed in which the sample was stratified according to median GRACE prognostic index score and median DASI scores. When stratifying patients around the median GRACE or DASI scores, the increase in health service consumption associated with depressive symptom burden was disproportionately higher among patients with lower GRACE scores (better cardiac prognostic risk) and higher DASI scores (greater functional capacity) than among their higher risk poorer functional capacity counterparts (Table 4).
The relative risks of health service utilization among those with (vs. without) depression after adjustment for baseline factors stratified by prognostic risk and functional capacity (among the entire AMI cohort, and among those in which death and recurrent AMI were excluded).*
Among the entire sample
Among those without death or re-infarction
Cardiac prognostic risk (GRACE Score⌷)
(n = 1079)
(n = 862)
(n = 995)
(n = 709)
Total hospitalization days#
1.11 (1.06 (1.18)
Total ER visits
Functional capacity (DASI score§
(n = 922)
(n = 1019)
(n = 856)
(n = 848)
Total hospitalization days#
Total ER visits
* All relative risks were adjusted for age, sex, income, pre-existing cardiovascular disease, pre-existing non-cardiovascular conditions, in-hospital processes of care, prognostic risk (GRACE and DASI). Abbreviation: AMI: Acute myocardial infarction. Interaction terms were included in models with the complete sample. Depression/GRACE score interactions were statistically significant for the following outcomes when death and recurrent AMI were included (General Practitioner (GP) Visits (P < 0.001) and when death and recurrent AMI were excluded: Total hospitalization days (P < 0.001); Total Cardiac-related hospitalization days (P < 0.001); Non-cardiac hospitalization days (P < 0.001); Cardiologist Visits (P = 0.02); Internist Visits (P = 0.05); GP visits (P < 0.001); and Total ER Counts (P = 0.002). Depression/DASI interactions were significant for the following outcomes when death and recurrent AMI were included: Total hospitalization days (P < 0.001); Non-cardiac hospitalization days (P < 0.001); GP Visits (P < 0.001); and Total Emergency Room (ER) Visits (P < 0.001). The depression/DASI interaction was also significant when death and recurrent AMI were excluded for the following outcomes: Total hospitalization days (P = 0.02); Non-cardiac hospitalization days (P = 0.004); GP Visits (P < 0.001) and Total ER Visits (P = 0.03). Depression status was based on the 9-item depression rating scale.
⌷ Abbreviation: GRACE – Global Registry of Acute Coronary Events.
§ Abbreviation: DASI – Duke Activity Status Index
□ Hospitalization days are a count of total days in hospital over the 18 month follow-up period and can accumulate from multiple hospitalizations.
# Total and cardiac hospitalization results excluded recurrent AMI hospitalizations.
Mortality and recurrent AMI
There was no significant difference in two-year mortality (HR = 0.92; 95% CI 0.59–1.42), re-AMI (HR = 1.22; 95% CI 0.89–1.66), or in the composite risk of death or recurrent AMI (Adjusted HR = 1.12; 95% CI 0.80–1.57) between patients with and without depressive symptoms.
First, the relationship between depression and health service consumption when using the 3 replacement items yielded similar outcomes as those generated with the 9-item BCDRS (see Additional file 1). Second variations in the cutoff scores used to distinguish depressive from non-depressive patients did not alter our results. For example, scores of 4 or 6 using the 9-item BCDRS generated similar results as a score of 5. Similarly, the use of the GUSTO quality of life sub-study depression measure scale yielded similar results as did our 9-item BCDRS. Finally, we used multiple imputation to repeat the analyses to include 888 subjects with missing depression scores, which did not substantively change the results from the complete data analyses (Figure 2).
Depressive symptoms at one-month post-AMI were significantly associated with health service consumption in the 18 months post-AMI. The relationship between health service consumption and depressive symptoms persisted after adjusting for comorbidity and cardiac illness severity. Indeed, the relationship between cardiac health service consumption and depressive symptoms was even greater among those patients with lower as compared with higher cardiac illness severity. In short, the increased likelihood of health service consumption among AMI patients were over and above that expected based on cardiac illness severity alone.
In our sample, depressive symptoms were not associated with increased mortality or recurrent AMI, which is contrary to previous evidence [26, 27]. However, the association between depression and cardiovascular outcomes remains controversial [28, 29] and the results of this study are not sufficient to address the controversial prognostic importance of depression definitively, especially given inter-study differences in measurement and timing of depression. It is conceivable that measuring depression at one-month post-AMI conferred a survival bias for which multiple imputation methods were unable to fully address. A recent publication measuring depression directly prior to one-month post-AMI found no association between depression and mortality at either time point after adjustment for covariates .
Our study demonstrated a significant interaction between depression, prognostic severity and health service consumption, such that higher health service use occurred among patients of lower rather than higher cardiac severity – a distinct contrast to those patients without depressive symptoms whose health service experiences better mirrored their cardiac illness severity levels. Available evidence has demonstrated a treatment-risk paradox whereby service provision is paradoxically most intensive among patients with lowest need [31, 32]. Our study suggests that the presence of depressive symptoms might partially mediate the treatment-risk paradox.
Some have hypothesized that mental illness and/or psychological phenomena such as somatization promote health seeking behaviors [6, 33]. Our results support such hypotheses. Indeed, in our study, depression-associated increases in the risk of recurrent hospitalization were no longer significant after adjusting for ER visits, suggesting that depression-readmission rates may be attributable to patient health-seeking behaviors more so than physicians' propensity to admit for more discretionary indications[34, 35].
Our study has several important clinical and policy implications. Patients with depressive symptoms post-AMI pose a serious challenge to physicians and health care systems. On one hand, such patients are sicker and may be more likely to die following AMI, underscoring the need for closer attentiveness and management. On the other hand, depressive patients consume significant amounts of cardiac health services and may do so disproportionately in relation to objective measures of prognostic or symptomatic burden. Integrated chronic cardiac care programs are well-established and effective interventions for patients post-AMI. Community-based depression interventions have also been shown to be effective at treating depression and improving quality of life. Given the benefits of both chronic vascular disease management, depression case-management and the high prevalence of depression in patients post-AMI, our study suggests that integrating depression screening and case-management into existing cardiac secondary prevention programs may be effective in improving the quality of life of depressed post-MI patients, and in reducing the apparent mismatch between need and service consumption. The importance of systematic depression screening is further underscored by the low detection rates of depression after AMI.
Our study has several noteworthy limitations. First, our scale was designed to ascertain depressive symptoms rather than depressive disorders and was missing 3 items from the original, validated depression rating scale. Our health service consumption findings were similar whether the 9 items or 3 replacement items were used to define depression. The comparability of results with these two depression measures suggests that the two scales are measuring the same construct. Second, depressive symptoms were measured cross-sectionally and at one-month post-AMI. As such, we could not determine the persistence of depressive symptoms over the follow-up interval. The delay in depression post-AMI also imposes a survival bias on the sample. However, survival bias is less of an issue with the main outcome of health service consumption, since service consumption differences are only relevant in those patients who survive long enough to use services. Finally, information regarding depression was missing in just over 30% of the potentially eligible respondent population. However, our sensitivity analyses utilizing model-based multiple imputation to include those patients with missing depression values provide evidence that the missing values did not materially affect our findings.
In conclusion, our study demonstrated the increased consumption of health services among post-AMI patients with depressive symptoms is independent of comorbidity and cardiac illness severity. Moreover, the interaction between depression, health service utilization, and prognosis such that increased cardiovascular health service consumption patterns among AMI patients with depressive symptoms was most pronounced among those of lower rather than higher cardiac illness severity suggests that cardiac health seeking behaviors among depressive patients may be mediated by psychosocial factors in addition to objective measures of need. Future research must evaluate whether systematic depression detection and integrated chronic disease management systems improve health service efficiency and allow for better alignment between illness severity and health service consumption among such patient populations.
The Socio-Economic and Acute Myocardial Infarction (SESAMI) study is supported by an operating grant from the Canadian Institutes of Health Research (CIHR). The SESAMI pilot study was supported by the 1988 Michael Smith Award of Excellence from the Medical Research Council of Canada. The Institute for Clinical Evaluative Sciences is supported in part by a grant from the Ontario Ministry of Health. Dr. Alter is a Career Scientist with the Heart and Stroke Foundation of Ontario. Dr. Kurdyak is supported by a CIHR Fellowship. None of the funding bodies had any involvement in study design; in the collection, analysis, and interpretation of data; in the writing of the manuscript; and in the decision to submit the manuscript for publication.
Institute for Clinical Evaluative Sciences (ICES)
Department of Psychiatry, University of Toronto
Health Systems Research and Consulting Unit, Centre for Addiction and Mental Health
Department of Health Policy, Management and Evaluation, University of Toronto
Division of Cardiology and the Li Ka Shing Knowledge Institute, St. Michael's Hospital
Department of Medicine, University of Toronto
Simon G, Ormel J, VonKorff M, Barlow W: Health care costs associated with depressive and anxiety disorders in primary care.American Journal of Psychiatry 1995, 152:352–357.PubMed
Unutzer J, Patrick DL, Simon G, Grembowski D, Walker E, Rutter C, Katon W: Depressive symptoms and the cost of health services in HMO patients aged 65 years and older. A 4-year prospective study.JAMA 1997, 277:1618–1623.View ArticlePubMed
Frasure-Smith N, Lesperance F, Gravel G, Masson A, Juneau M, Talajic M, Bourassa MG: Depression and health-care costs during the first year following myocardial infarction.J Psychosom Res 2000, 48:471–478.View ArticlePubMed
Jiang W, Alexander J, Christopher E, Kuchibhatla M, Gaulden LH, Cuffe MS, Blazing MA, Davenport C, Califf RM, Krishnan RR, O'Connor CM: Relationship of depression to increased risk of mortality and rehospitalization in patients with congestive heart failure.Arch Intern Med 2001, 161:1849–1856.View ArticlePubMed
Lett HS, Blumenthal JA, Babyak MA, Sherwood A, Strauman T, Robins C, Newman MF: Depression as a risk factor for coronary artery disease: evidence, mechanisms, and treatment.Psychosomatic Medicine 2004, 66:305–315.View ArticlePubMed
Katon W: The impact of major depression on chronic medical illness.Gen Hosp Psychiatry 1996, 18:215–219.View ArticlePubMed
Fox KA, Dabbous OH, Goldberg RJ, Pieper KS, Eagle KA, Werf F, Avezum A, Goodman SG, Flather MD, Anderson FAJ, Granger CB: Prediction of risk of death and myocardial infarction in the six months after presentation with acute coronary syndrome: prospective multinational observational study (GRACE).BMJ 2006, 333:1091.View ArticlePubMed
Granger CB, Goldberg RJ, Dabbous O, Pieper KS, Eagle KA, Cannon CP, Werf F, Avezum A, Goodman SG, Flather MD, Fox KA: Predictors of hospital mortality in the global registry of acute coronary events.Arch Intern Med 2003, 163:2345–2353.View ArticlePubMed
Chen J, Rathore SS, Radford MJ, Wang Y, Krumholz HM: Racial differences in the use of cardiac catheterization after acute myocardial infarction.New England Journal of Medicine 2001, 344:1443–1449.View ArticlePubMed
Alter DA, Iron K, Austin PC, Naylor CD: Socioeconomic status, service patterns, and perceptions of care among survivors of acute myocardial infarction in Canada.JAMA 2004, 291:1100–1107.View ArticlePubMed
Koenig HG, Meador KG, Cohen HJ, Blazer DG: Self-rated depression scales and screening for major depression in the older hospitalized patient with medical illness.Journal of the American Geriatrics Society 1988, 36:699–706.PubMed
Association APWashington, DC: American Psychiatric Association 2000.
Mark DB, Naylor CD, Hlatky MA, Califf RM, Topol EJ, Granger CB, Knight JD, Nelson CL, Lee KL, Clapp-Channing NE, et al.: Use of medical resources and quality of life after acute myocardial infarction in Canada and the United States.New England Journal of Medicine 1994, 331:1130–1135.View ArticlePubMed
Alter DA, Brandes S, Irvine J, Iron K: Impact of socioeconomic status on cardiovascular outcomes in Canada.Expert Review of Pharmacoeconomics Outcomes Research 2003, 3:691–702.View ArticlePubMed
Alter DA, Venkatesh V, Chong A: Evaluating the performance of the Global Registry of Acute Coronary Events risk-adjustment index across socioeconomic strata among patients discharged from the hospital after acute myocardial infarction.American Heart Journal 2006, 151:323–331.View ArticlePubMed
Hlatky MA, Boineau RE, Higginbotham MB, Lee KL, Mark DB, Califf RM, Cobb FR, Pryor DB: A brief self-administered questionnaire to determine functional capacity (the Duke Activity Status Index).American Journal of Cardiology 1989, 64:651–654.View ArticlePubMed
Vanhees L, Fagard R, Thijs L, Staessen J, Amery A: Prognostic significance of peak exercise capacity in patients with coronary artery disease.Journal of the American College of Cardiology 1994, 23:358–363.View ArticlePubMed
Gravely-Witte S, Stewart DE, Suskin N, Higginson L, Alter DA, Grace SL: Cardiologists' charting varied by risk factor, and was often discordant with patient report.J Clin Epidemiol 2008,61(10):1073–1079.View ArticlePubMed
Alter DA, Chong A, Austin PC, Mustard C, Iron K, Williams JI, Morgan CD, Tu JV, Irvine J, Naylor CD: Socioeconomic status and mortality after acute myocardial infarction.Annals of Internal Medicine 2006, 144:82–93.PubMed
Zhang JX, Iwashyna TJ, Christakis NA: The performance of different lookback periods and sources of information for Charlson comorbidity adjustment in Medicare claims.Medical Care 1999, 37:1128–1139.View ArticlePubMed
Sytkowski PA, Kannel WB, D'Agostino RB: Changes in risk factors and the decline in mortality from cardiovascular disease. The Framingham Heart Study.New England Journal of Medicine 1990, 322:1635–1641.View ArticlePubMed
Kerr EA, Heisler M, Krein SL, Kabeto M, Langa KM, Weir D, Piette JD: Beyond comorbidity counts: how do comorbidity type and severity influence diabetes patients' treatment priorities and self-management?Journal of General Internal Medicine 2007, 22:1635–1640.View ArticlePubMed
Austin PC, Daly PA, Tu JV: A multicenter study of the coding accuracy of hospital discharge administrative data for patients admitted to cardiac care units in Ontario.American Heart Journal 2002, 144:290–296.View ArticlePubMed
Little RJA, Rubin D: Statistical analysis with missing data.2 Edition New York: Wiley 2002.
Frasure-Smith N, Lesperance F, Talajic M: Depression and 18-month prognosis after myocardial infarction.Circulation 1995, 91:999–1005.PubMed
van Melle JP, de Jonge P, Spijkerman TA, Tijssen JG, Ormel J, van Veldhuisen DJ, Brink RH, Berg MP: Prognostic association of depression following myocardial infarction with mortality and cardiovascular events: a meta-analysis.Psychosomatic Medicine 2004, 66:814–822.View ArticlePubMed
Lane D, Carroll D, Ring C, Beevers DG, Lip GY: Mortality and quality of life 12 months after myocardial infarction: effects of depression and anxiety.Psychosomatic Medicine 2001, 63:221–230.PubMed
Sorensenf C, Friis-Hasche E, Haghfelt T, Bech P: Postmyocardial infarction mortality in relation to depression: a systematic critical review.Psychother Psychosom 2005, 74:69–80.View ArticlePubMed
Dickens C, McGowan L, Percival C, Tomenson B, Cotter L, Heagerty A, Creed F: Depression is a risk factor for mortality after myocardial infarction: fact or artifact?Journal of the American College of Cardiology 2007, 49:1834–1840.View ArticlePubMed
Ko DT, Mamdani M, Alter DA: Lipid-lowering therapy with statins in high-risk elderly patients: the treatment-risk paradox.JAMA 2004, 291:1864–1870.View ArticlePubMed
Lee DS, Tu JV, Juurlink DN, Alter DA, Ko DT, Austin PC, Chong A, Stukel TA, Levy D, Laupacis A: Risk-treatment mismatch in the pharmacotherapy of heart failure.JAMA 2005, 294:1240–1247.View ArticlePubMed
Barsky AJ, Orav EJ, Bates DW: Somatization increases medical utilization and costs independent of psychiatric and medical comorbidity.Arch Gen Psychiatry 2005, 62:903–910.View ArticlePubMed
Guadagnoli E, Hauptman PJ, Ayanian JZ, Pashos CL, McNeil BJ, Cleary PD: Variation in the use of cardiac procedures after acute myocardial infarction.New England Journal of Medicine 1995, 333:573–578.View ArticlePubMed
Muller DW, Topol EJ, Califf RM, Sigmon KN, Gorman L, George BS, Kereiakes DJ, Lee KL, Ellis SG: Relationship between antecedent angina pectoris and short-term prognosis after thrombolytic therapy for acute myocardial infarction. Thrombolysis and Angioplasty in Myocardial Infarction (TAMI) Study Group.American Heart Journal 1990, 119:224–231.View ArticlePubMed
Clark AM, Hartling L, Vandermeer B, McAlister FA: Meta-analysis: secondary prevention programs for patients with coronary artery disease.Annals of Internal Medicine 2005, 143:659–672.PubMed
Ciechanowski P, Wagner E, Schmaling K, Schwartz S, Williams B, Diehr P, Kulzer J, Gray S, Collier C, LoGerfo J: Community-integrated home-based depression treatment in older adults: a randomized controlled trial.JAMA 2004, 291:1569–1577.View ArticlePubMed
Thombs BD, Bass EB, Ford DE, Stewart KJ, Tsilidis KK, Patel U, Fauerbach JA, Bush DE, Ziegelstein RC: Prevalence of depression in survivors of acute myocardial infarction.Journal of General Internal Medicine 2006, 21:30–38.View ArticlePubMed
Amin AA, Jones AMH, Nugent K, Rumsfeld JS, Spertus JA: The prevalence of unrecognized depression in patients with acute coronary syndrome.American Heart Journal 2006, 152:928–934.View ArticlePubMed
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