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Research Report - Final – May 22, 2008

Observed Association Between Antidepressant Use and Pneumonia Risk Was Confounded by Comorbidity Measures

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Author Affiliations

Sean Hennessy, Pharm.D., Ph.D.1, 2, 3
Warren B. Bilker, Ph.D.1, 2, 3
Charles E. Leonard, Pharm.D.1, 2, 3
Jesse Chittams, M.S.1, 2, 3
Cristin M. Palumbo, M.P.H.1, 2, 3
Jason H. Karlawish, M.D.1, 4
Yu-Xiao Yang, M.D., M.S.C.E.1, 3, 4
Ebbing Lautenbach, M.D., M.P.H., M.S.C.E.1, 2, 3, 4
William B. Baine, M.D.5
Joshua P. Metlay, M.D., Ph.D.1, 2, 3, 4, 6

1 Center for Clinical Epidemiology and Biostatistics, University of Pennsylvania School of Medicine, Philadelphia, PA.
2 Developing Evidence to Inform Decisions about Effectiveness (DEcIDE) Center, University of Pennsylvania School of Medicine, Philadelphia, PA.
3 Center for Education and Research on Therapeutics, University of Pennsylvania School of Medicine, Philadelphia, PA.
4 Department of Medicine, University of Pennsylvania School of Medicine, Philadelphia, PA.
5 Center for Outcomes and Evidence, Agency for Healthcare Research and Quality, U.S. Department of Health and Human Services, Rockville, MD.
6 Department of Veterans Affairs, Philadelphia, PA.

Identifiable information on which this report, presentation, or other form of disclosure is based is confidential and protected by Federal law, section 903(c) of the Public Health Service Act, 42 U.S.C. 299a-1(c). Any identifiable information that is knowingly disclosed is disclosed solely for the purpose for which it has been supplied. No identifiable information about any individual supplying the information or described in it will be knowingly disclosed except with the prior consent of that individual.

Abstract

Objective: A prior study suggested that antidepressants might increase the risk of hospitalization for pneumonia in the elderly. This study sought to confirm or refute this hypothesis.

Study Design and Setting: Case-control study of persons age 65 and above nested in the UK General Practice Research Database.

Results: We identified 12,044 cases of the hospitalization for pneumonia (the primary outcome) and 48,176 controls. The odds ratio (OR) for any antidepressant use, adjusting for age, sex, and calendar year was 1.61 (95% confidence interval 1.46 to 1.78). After further adjustment for comorbidity measures, the OR was 0.89 (0.79 to 1.00). We also identified 159 cases of hospitalization for aspiration pneumonia (the secondary outcome) and 636 controls. The OR for any antidepressant use, adjusted for age, sex, and calendar year was 1.45 (0.65 to 3.24). After further adjustment for comorbidity measures, the OR was 0.63 (0.23 to 1.71).

Conclusion: These findings refute the prior hypothesis that use of antidepressants by elderly patients increases the risk of hospitalization for pneumonia or for aspiration pneumonia. Decisions regarding use of antidepressants in elderly persons should not be affected by concern about pneumonia risk. Data-derived hypotheses should be independently confirmed before being acted upon.

Keywords: aged; antidepressive agents; pneumonia; pneumonia, aspiration; pharmacoepidemiology.

Introduction

Pneumonia is a major cause of morbidity and mortality in the elderly. Together with influenza, pneumonia constitutes the fifth leading cause of death in those age 65 years and older in the US, behind heart disease, cancer, stroke, and chronic lower respiratory diseases [1]. The incidence of hospitalization for pneumonia for those age 65 years and older in the US increased by 20% from 1988 to 2002 [2]. One major etiologic factor for pneumonia in the elderly is aspiration of oropharyngeal contents [3,4]. Although the clinical diagnosis of aspiration as a cause of pneumonia is often uncertain [4,5], the incidence of hospitalization for diagnosed aspiration pneumonia in US elderly nearly doubled between 1991 and 1998 [6].

A recent study undertaken to identify possible signals of iatrogenic illness in the elderly found that hospitalization for aspiration pneumonia was three times as likely to occur in the ninety-day period following a hospitalization for depression as in the ninety-day period preceding a hospitalization for depression [7], leading to the hypothesis that antidepressant drugs may increase the risk of aspiration pneumonia. If true, such an effect could have major therapeutic implications for the treatment of elderly depressed patients, since the benefit of pharmacotherapy would need to be weighed against the risk of aspiration pneumonia, a serious outcome. However, this prior study was limited in that it identified diagnoses occurring disproportionately after vs. before hospitalizations for depression in order to identify potential signals. It did not measure exposure to antidepressants or attempt to control for patient factors that may change over time.

The objective of this study was to evaluate the hypothesis that antidepressant use in the elderly is associated with hospitalization for pneumonia (our primary aim) or hospitalization for aspiration pneumonia or pneumonitis (our secondary aim).

Subjects and Methods

2.1. Overview and Study Population

We performed an observational case-control study nested within the General Practice Research Database (GPRD) from the UK. GPRD data constitute the primary outpatient electronic medical records from approximately two thousand general practitioners (GPs) in the UK. Within the UK, approximately 98% of the population is registered with a GP, and virtually all patient care is coordinated by the GP through the National Health Service. The database is broadly representative of the UK population in terms of age, sex, and geography. More than 500 published epidemiologic studies have been performed using this database. The GPRD records outpatient prescriptions, outpatient diagnoses, and hospital diagnoses that are entered in response to receipt of a consultant's letter or discharge summary [8]. We used GPRD data entered from its establishment in 1987 through April 2002, and included only data classified as "up-to-standard" for identifying exposures and outcomes [8].

2.2. Study Base

The person-time eligible for inclusion in this nested case-control study (i.e., the study base within which the case-control study was nested) was all up-to-standard person-time occurring in individuals age 65 years and above with at least six months of prior up-to-standard follow-up in whom no instance of the study outcome had yet occurred. We required at least six months of data prior to study eligibility to ensure an adequate period in which to measure baseline variables. Cases and controls were sampled from this study base using incidence density sampling, as described below, which results in odds ratios (ORs) that are interpretable as incidence rate ratios [9].

2.3. Identification of Cases

Cases of the primary outcome consisted of all individuals who were hospitalized with pneumonia at any time following the six month anniversary date of that person's up-to-standard entry date. Cases of the secondary outcome consisted of persons who were hospitalized with aspiration pneumonia or aspiration pneumonitis at any time following the six month anniversary date of that person's up-to-standard entry date. The index date for cases was the date of the case event. For persons with more than one case event, we included only the first event. Diagnostic codes for the study outcomes are listed in the Appendix.

2.4. Identification of Controls

For each case, we randomly selected four controls from the same GP practice using incidence density sampling [9] based on amount of time in the study base. In particular, potential controls were persons who contributed person-time to the study base (defined above), who had not yet experienced the relevant study outcome before the corresponding case's event, assessed with respect to entry into the study base. The index date for controls was defined as the date of entry into the study base plus the number of days of event-free follow-up contributed by the corresponding case. This is analogous to time-to-event analyses of cohort studies, and ensures the interpretability of the resulting odds ratios as incidence rate ratios [9].

2.5. Ascertainment of Exposure

The principal exposure definition was a recorded prescription for any antidepressant medication in the thirty days preceding the index date. Prescriptions for chronically administered medications in the UK are issued in one-month increments. In order to obtain repeat prescriptions (i.e., prescription refills), patients must telephone or visit the GP office, which then issues and records a repeat prescription. To confirm the tendency to provide a one-month supply per prescription, we examined the frequency distribution of the number of days between subsequent prescriptions for commonly used antidepressants for the same patient. There was a very strong central tendency (i.e., mode and median) for repeat prescriptions to be issued approximately every thirty days (data not shown). In addition to considering exposure to any antidepressant, we also performed sub-analyses of the two major subclasses: cyclic agents (amitriptyline, amoxapine, butriptyline, clomipramine, desipramine, dibenzepin, dosulepin, doxepin, imipramine, iprindole, lofepramine, maprotiline, mianserin, mirtazapine, nortriptyline, opipramol, protriptyline, trimipramine) and selective serotonin uptake inhibitors and selective serotonin and norepinephrine inhibitors (SSRI/SSNRIs; citalopram, duloxetine, escitalopram, fluoxetine, fluvoxamine, paroxetine, sertraline, venlafaxine, zimeldine).

2.6. Ascertainment of Potential Confounding Factors

Potential confounding factors were ascertained based on the index date. These are listed in Tables 1 and 2, and included demographic factors, diagnoses ever recorded in the past (focusing on conditions previously implicated as risk factors for pneumonia, including chronic neurologic and pulmonary conditions [4]), drug prescribed ever in the past (as markers of disease), currently prescribed drugs (i.e., within the past thirty days), and measures of morbidity and health care utilization (e.g., number of non-antidepressant prescriptions in the prior thirty days, number of GP visits for non-depression diagnoses in the prior thirty days, number of hospitalizations in the prior six months).

2.7. Statistical Analysis

We first compared cases to controls with respect to antidepressant exposure and potential confounding factors. We next used conditional logistic regression to fit a "minimally adjusted" model that estimated the odd ratio (OR) for antidepressant use adjusting for age (expressed as a continuous variable), sex, and calendar year (to account for potential secular trends in pneumonia hospitalization and antidepressant use). We then examined each potential confounding factor individually using a change-in-estimate criterion [10]. In particular, we individually added each potential confounding factor to the minimally adjusted model. If any factor changed the OR of interest by ten percent or more, we considered it to be a confounding factor and retained it in the "change-in-estimate" adjusted model. We used this same strategy to examine the association with each antidepressant subclass. However, because of the small number of events of the secondary outcome (aspiration pneumonia), we were unable to examine associations for this outcome with specific antidepressant subclasses. We used SAS version 9.1 for all analyses.

The incidence of pneumonia is expected to peak during the winter months and decline during the summer, whereas antidepressant therapy might be prescribed year-round. We compared the seasonal distribution of hospitalization for pneumonia in patients with and without exposure to antidepressants using the method of Edwards [11]. This sums the vectors for the number of cases in each month extending from a common origin to the midpoints of twelve equal sectors of a circle from January (0 to 30°) through December (330 to 360°).

Based on pilot data, our a priori power calculations suggested that using a two-tailed α of 5%, we would have 85% statistical power to detect an OR for exposure to any antidepressant of 1.07 or higher for pneumonia hospitalization, and an OR of 1.5 or higher for hospitalization for aspiration pneumonia or pneumonitis [12].

Results

3.1. Primary Outcome: Hospitalization for Pneumonia

We identified 12,044 cases of hospitalization for pneumonia. For each case, we identified four controls, for a total of 48,176 controls. Table 1 presents a comparison of cases and controls for the primary outcome. Cases were older than controls (median age 81 vs. 75), and had a substantially higher number of non-depression GP visits in the prior six months (average 2.8 vs. 0.8), hospital visits over the prior six months (mean 0.72 vs. 0.13), and number of non-antidepressant prescriptions in the prior month (mean 3.6 vs. 2.0). Most diagnoses, drugs prescribed ever in the past, and currently prescribed drugs examined were substantially more common among cases than controls (Table 1).

The OR (95% CI) for the association between pneumonia hospitalization and any antidepressant use, adjusted for age, sex, and calendar year (i.e., the minimally adjusted model) was 1.61 (1.46 to 1.78). However, when further adjusting for factors in Table 1 that changed the OR by ten percent or more (number of non-depression GP visits in the prior six months, ever past benzodiazepine prescription, and ever past antipsychotic prescription) the OR (95% CI) was 0.89 (0.79 to 1.00) (Table 1).

In the analysis of the major antidepressant subclasses, the ORs for cyclic antidepressants, SSRIs/SSNRIs, and other agents were similar to the corresponding OR for any antidepressant in baseline model (Table 1). The change-in-estimate adjusted ORs for cyclic agents and SSRI/SSNRIs were also similar to the corresponding OR for antidepressants as a whole (Table 1).

The seasonal vector of hospitalization for pneumonia in patients without prescriptions for antidepressants showed the expected pronounced wintertime peak (0.088 units at 27°, i.e., late January). This vector was closely matched in both relative amplitude and direction (0.103 units at 23°) by that of hospitalization for pneumonia in patients who were receiving antidepressants (data not shown).

3.2. Secondary Outcome: Hospitalization for Aspiration Pneumonia or Aspiration Pneumonitis

We identified 159 cases of hospitalization for diagnosed aspiration pneumonia or pneumonitis, and 636 controls. Table 2 presents a comparison of cases and controls for the secondary outcome. The relationships of the factors presented in Table 2 with hospitalization for aspiration pneumonia or pneumonitis were similar to those seen for the primary outcome, although the confidence intervals are much wider in Table 2 because of the small number of events. The OR (95% CI) for any antidepressant use, adjusted for age, sex, and calendar year was 1.45 (0.65 to 3.24). When further adjusting for factors in Table 2 that changed the OR by ten percent or more (number of non-depression GP visits in the prior six months, ever past benzodiazepine prescription, and ever past antipsychotic prescription) the OR (95% CI) was 0.63 (0.23 to 1.71) (Table 2). There were not enough users of specific antidepressant subclasses with this outcome to analyze these subclasses separately.

Discussion

The purpose of this study was to further evaluate the hypothesis that antidepressants may increase the risk of hospitalization for aspiration pneumonia in the elderly [7]. This signal arose in the context of a systematic process to screen for iatrogenic factors that may lead to depression, and for complications of depression treatment. The positive association that we observed between antidepressants and pneumonia hospitalization, the primary outcome, before adjusting for clinical variables, is consistent with, but somewhat lower than (1.6 vs. 3.0) the earlier signal that hospitalization for aspiration pneumonia in the elderly is more common after than before a hospitalization for depression. In other words, pneumonia hospitalization does indeed seem to be more common in antidepressant users. However, the earlier study [7] screened administrative claims data with the goal of identifying a potential wide range of potential signals to be further tested, did not measure actual exposure to antidepressant drugs, and made no attempt to control for patient factors that may change over time. In contrast, the current study focused on examining a particular association, with an emphasis on controlling for confounding.

The results of this study are reassuring that, once comorbidity measures are taken into account, there is no evidence that antidepressants increase the risk of hospitalization for pneumonia in the elderly. This is true for the general class of antidepressants and specifically for cyclic agents and SSRIs/SSNRIs. This conclusion is reinforced by the observation that the occurrence of pneumonia in patients prescribed antidepressants did not deviate from the expected wintertime peak in incidence. In addition to following up a potential signal, and in the process providing reassurance about the safety of antidepressants with regard to pneumonia in the elderly, this study confirms earlier findings that increasing age and the presence of co-morbidities are strongly associated with pneumonia [13-17].

This study has limitations. Although the GPRD is derived from the primary medical record, and diagnoses recorded in the GPRD are generally regarded as being of high quality [8], these study outcomes have not been specifically validated. However, misclassification of the outcome seems unlikely to be responsible for our negative findings because there was a positive association between antidepressants and pneumonia in the minimally adjusted analysis. In addition, we did confirm associations with pulmonary and neurologic conditions, and other factors that would be expected to be associated with pneumonia. Exposure misclassification could also have played a role, in that patients prescribed antidepressant drugs might not take them, which could have tended to produce bias toward the null. However, exposure misclassification would have resulted in bias toward the null in both the unadjusted and adjusted analyses. Because of the large number of cases of hospitalization for depression, and the narrow CIs for this effect estimate, type-2 error is unlikely to have played a prominent role in the primary outcome. However, as we recognized at the outset, type-2 error is more of a concern for the secondary outcome.

In conclusion, we performed a controlled epidemiologic study to follow up on a prior data-derived hypothesis that, if true, could have had important therapeutic implications for elderly patients with depression. Although there was indeed an unadjusted association between antidepressant medication use and pneumonia hospitalization, the observed association appeared to be due to confounding by measured co-morbidity measures. This reinforces the need to independently confirm data-derived hypotheses before acting on them.

Acknowledgments

Dr. Hennessy is also supported by the National Institute on Aging (K23AG000987), and Dr. Yang is also supported by the National Institute of Diabetes and Kidney Diseases (K08DK062978). The authors acknowledge Maximilian Herlim for his statistical programming.

References

[1] Gorina Y, Hoyert D, Lentzner H, et al. Trends in causes of death among older persons in the United States. Aging Trends, No 6. 2006. Hyattsville, MD, National Center for Health Statistics.

[2] Fry AM, Shay DK, Holman RC, et al. Trends in hospitalizations for pneumonia among persons aged 65 years or older in the United States, 1988-2002. Chest 2005;294:2712-19.

[3] Yamaya M, Yanai M, Ohrui T, et al. Interventions to prevent pneumonia among older adults. J Am Geriatr Soc 2001;49:85-90.

[4] Marik PE, Kaplan D. Aspiration pneumonia and dysphagia in the elderly. Chest 2003;124:328-36.

[5] Marik PE. Aspiration pneumonitis and aspiration pneumonia. N Engl J Med 2001;344:665-71.

[6] Baine WB, Yu W, Summe JP. Epidemiologic trends in the hospitalization of elderly Medicare patients for pneumonia, 1991-1998. Am J Public Health 2001;91:1121-23.

[7] Baine WB, Kazakova SV. An analysis of administrative data found that proximate clinical event ratios provided a systematic approach to identifying possible iatrogenic risk factors or complications. J Clin Epidemiol 2005;58:162-70.

[8] Garcia Rodriguez LA, Perez GS. Use of the UK General Practice Research Database for pharmacoepidemiology. Br J Clin Pharmacol 1998;45:419-25.

[9] Flanders WD, Louv WC. The exposure odds ratio in nested case-control studies with competing risks. Am J Epidemiol 1986;124:684-92.

[10] Mickey RM, Greenland S. The impact of confounder selection criteria on effect estimation. Am J Epidemiol 1989;129:125-37.

[11] Edwards JH. The recognition and estimation of cyclic trends. Ann Hum Genet 1961;25:83-6.

[12] Dupont WD, Plummer WD Jr. Power and sample size calculations. A review and computer program. Control Clin Trials 1990;11:116-28.

[13] Almirall J, Bolibar I, Balanzo X, et al. Risk factors for community-acquired pneumonia in adults: a population-based case-control study. Eur Respir J 1999;13:349-55.

[14] Farr BM, Bartlett CL, Wadsworth J, et al, for the British Thoracic Society Pneumonia Study Group. Risk factors for community-acquired pneumonia diagnosed upon hospital admission. Respir Med 2000;94:954-63.

[15] Farr BM, Woodhead MA, Macfarlane JT, et al. Risk factors for community-acquired pneumonia diagnosed by general practitioners in the community. Respir Med 2000;94:422-7.

[16] Laheij RJ, Sturkenboom MC, Hassing RJ, et al. Risk of community-acquired pneumonia and use of gastric acid-suppressive drugs. Chest 2004;292:1955-60.

[17] Langmore SE, Skarupski KA, Park PS, et al. Predictors of aspiration pneumonia in nursing home residents. Dysphagia 2002;17:298-307.

Tables

Table 1. Characteristics of cases and controls of hospitalization for pneumonia
Characteristic Cases
(N = 12,044)
Controls
(N = 48,176)
* Adjusted for age, sex, calendar year, and current use of an antidepressant drug.
† Adjusted for age, sex, calendar year, and any factor in Table 1 that changed the OR for exposure by ten percent or more.
‡ Adjusted for age, sex, calendar year, number of non-depression GP visits in the prior six months, ever past benzodiazepine prescription, and ever past antipsychotic prescription
§ Adjusted for age, sex, calendar year, number of non-depression GP visits in prior six months, number of non-antidepressant prescriptions in the prior month, ever past benzodiazepine prescription, and ever past antipsychotic prescription
SD denotes standard deviation
GP denotes general practitioner
OR denotes matched odds ratio
CI denotes confidence interval
SSRI/SSNRI denotes selective serotonin reuptake inhibitor / selective serotonin and norepinephrine reuptake inhibitor
Median age in years (interquartile range) 81 (74 to 86) 75 (70 to 81)    
Mean (SD) number of nondepression visits in prior six months 2.8 (3.1) 0.8 (1.6)    
Mean (SD) number of nonantidepressant prescriptions in prior month 3.6 (4.1) 2.0 (2.9)    
Mean (SD) number of hospital visits over prior six months 0.72 (1.13) 0.13 (0.49)    
Characteristic Cases N (%) Controls N (%) Minimally adjusted OR (95% CI)* Change-in-estimate adjusted OR (95% CI)
Male sex 5836 (48.5) 18484 (40.4) 1.71 (1.63 to 1.78)  
Alcohol use 2882 (23.9) 15846 (32.9) 0.71 (0.68 to 0.75)  
Current smoking 3079 (25.6) 10915 (22.7) 1.57 (1.49 to 1.65)  
Diagnoses ever in past Anterior horn motor neuron disease 30 (0.3) 20 (0.04) 7.29 (3.95 to 13.47)  
Anxiety 1433 (11.9) 5099 (10.6) 1.30 (1.22 to 1.39)  
Bipolar disorder 33 (0.3) 76 (0.2) 2.50 (1.61 to 3.88)  
Chronic obstructive pulmonary disease 2436 (20.2) 2992 (6.2) 3.92 (3.67 to 4.18)  
Cerebrovascular disease 2096 (17.4) 3829 (8.0) 2.04 (1.91 to 2.17)  
Depression 2438 (20.2) 6730 (14.0) 1.75 (1.65 to 1.86)  
Dysphagia 454 (3.8) 881 (1.8) 2.10 (1.85 to 2.38)  
Herpetic neuralgia / herpes zoster 916 (7.6) 3243 (6.7) 1.15 (1.06 to 1.25)  
Insomnia 2712 (22.5) 7083 (14.7) 1.55 (1.46 to 1.63)  
Parkinson's disease 220 (1.8) 355 (0.7) 1.82 (1.52 to 2.19)  
Poor nutritional status 120 (1.0) 153 (0.3) 2.84 (2.18 to 3.70)  
Schizophrenic disorders 64 (0.5) 220 (0.5) 1.49 (1.11 to 2.00)  
Senile dementia 536 (4.5) 636 (1.3) 2.24 (1.97 to 2.54)  
Suicidal ideation 7 (0.1) 19 (0.0) 1.98 (0.78 to 5.07)  
Drugs prescribed in past Antiparkinsonian 551 (4.6) 842 (1.8) 2.24 (1.99 to 2.53)  
Antipsychotic 3394 (28.2) 9233 (19.2) 1.59 (1.51 to 1.67)  
Barbiturate 97 (0.8) 208 (0.4) 1.73 (1.33 to 2.24)  
Benzodiazepine 3974 (33.0) 10300 (21.4) 1.79 (1.71 to 1.88)  
Histamine H-2 receptor antagonist 2844 (23.6) 8162 (16.9) 1.60 (1.51 to 1.68)  
Mood stabilizer 49 (0.4) 131 (0.3) 1.91 (1.35 to 2.71)  
Opiate 2760 (22.9) 7072 (14.7) 1.93 (1.83 to 2.04)  
Proton pump inhibitor 1251 (10.4) 3584 (7.4) 1.68 (1.56 to 1.81)  
Currently prescribed drugs Antidepressant 687 (5.7) 1643 (3.4) 1.61 (1.46 to 1.78) 0.89 (0.79 to 1.00)

Cyclic 487 (4.04) 1198 (2.49) 1.57 (1.40 to 1.77) 0.92 (0.80 to 1.05)§

SSRI/SSNRI 183 (1.52) 399 (0.83) 1.65 (1.36 to 1.99) 0.86 (0.69 to 1.07)§

Antiparkinsonian 215 (1.8) 430 (0.9) 1.61 (1.35 to 1.92)  
Antipsychotic 736 (6.1) 1290 (2.7) 1.82 (1.64 to 2.02)  
Barbiturate 46 (0.4) 102 (0.2) 1.64 (1.13 to 2.38)  
Benzodiazepine 1377 (11.4) 3265 (6.8) 1.55 (1.44 to 1.67)  
Histamine H-2 receptor antagonist 651 (5.4) 1749 (3.6) 1.37 (1.25 to 1.52)  
Mood stabilizer 17 (0.1) 60 (0.1) 1.19 (0.68 to 2.09)  
Opiate 576 (4.8) 740 (1.5) 3.29 (2.91 to 3.71)  
Proton pump inhibitor 437 (3.6) 1104 (2.3) 1.76 (1.55 to 1.99)  
Table 2. Characteristics of cases and controls of hospitalization for aspiration pneumonia or aspiration pneumonitis
Characteristic Cases
(N = 159)
Controls
(N = 636)
* Adjusted for age, sex, calendar year, and current use of an antidepressant drug
Adjusted for age, sex, calendar year, and any factor in Table 1 that changed the OR for exposure by ten percent or more.
‡ Adjusted for age, sex, calendar year, chronic obstructive pulmonary disease, dysphagia, senile dementia, ever past antipsychotic prescription, ever past benzodiazepine prescription, and current anti-parkinsonian agent
SD denotes standard deviation
GP denotes general practitioner
OR denotes matched odds ratio
CI denotes confidence interval
SSRI/SSNRI denotes selective serotonin reuptake inhibitor / selective serotonin and norepinephrine reuptake inhibitor
Median age in years (interquartile range) 80 (75 to 86) 77 (72 to 82)    
Mean (SD) number of GP non-depression visits in prior six months 3.16 (3.03) 0.84 (1.65)    
Mean (SD) number of nonantidepressant  prescriptions in  month 4.09 (5.02) 2.33 (3.20)    
Mean (SD) number of hospital visits over prior six months 1.09 (1.38) 0.15 (0.61)    
Characteristic Cases N (%) Controls N (%) Minimally adjusted OR (95% CI)* Change-in-estimate adjusted OR (95% CI)
Male sex 84 (52.8) 211 (36.0) 2.57 (1.72 to 3.84)  
Alcohol use 44 (27.7) 204 (32.1) 0.70 (0.44 to 1.11)  
Smoking 40 (25.2) 146 (23.0) 1.22 (0.76 to 1.97))  
Diagnoses ever in past Anterior horn motor neuron disease 4 (2.5) 0 (0.0) inestimable  
Anxiety 22 (13.8) 77 (12.1) 1.43 (0.82 to 2.48)  
Bipolar disorder 0 (0.0) 2 (.03) inestimable  
Chronic obstructive pulmonary disease 29 (18.2) 47 (7.4) 2.91 (1.66 to 5.09)  
Cerebrovascular disease 65 (40.9) 69 (10.9) 5.64 (3.51 to 9.05)  
Depression 35 (22.0) 101 (15.9) 1.74 (1.03 to 2.95)  
Dysphagia 27 (17.0) 8 (1.3) 23.11 (8.30 to 64.36))  
Herpetic neuralgia / herpes zoster 17 (10.7) 49 (7.7) 1.77 (0.93 to 3.37)  
Insomnia 35 (22.0) 126 (19.8) 1.27 (0.78 to 2.08)  
Parkinson's disease 6 (3.8) 4 (0.6) 6.91 (1.69 to 28.3)  
Poor nutritional status 7 (4.4) 2 (0.3) 13.92 (2.67 to 72.69)  
Schizophrenic disorders 2 (1.3) 1 (0.2) 30.42 (2.19 to 423.2)  
Senile dementia 11 (6.9) 9 (1.4) 3.39 (1.26 to 9.10)  
Suicidal ideation 1 (0.6) 1 (0.2) 10.01 (0.49 to 205.8)  
Drugs prescribed ever in past Antipsychotic 57 (35.9) 141 (22.2) 2.04 (1.33 to 3.14)  
Antiparkinsonian 15 (9.4) 6 (0.9) 10.81 (3.72 to 31.42)  
Barbiturate 2 (1.3) 6 (0.9) 2.32 (0.39 to 13.95)  
Benzodiazepine 54 (34.0) 163 (25.6) 1.91 (1.25 to 2.93)  
Histamine H-2 receptor antagonist 45 (28.3) 131 (20.6) 1.56 (1.02 to 2.39)  
Mood stabilizer 4 (2.5) 2 (0.3) 4.56 (0.74 to 28.24)  
Opiate 39 (24.5) 116 (18.2) 1.89 (1.18 to 3.03)  
Proton pump inhibitor 31 (19.5) 57 (9.0) 2.55 (1.48 to 4.38)  
Currently prescribed drugs Antidepressant 11 (6.9) 28 (4.4) 1.45 (0.65 to 3.24) 0.63 (0.23 to 1.71)

Cyclic 6 (3.8) 23 (3.6)    
SSRI/SSNRI 4 (2.5) 5 (0.8)    
Antipsychotic 12 (7.6) 25 (3.9) 1.43 (0.64 to 3.22)  
Antiparkinsonian 5 (3.1) 2 (0.3) 6.16 (1.09 to 34.81)  
Barbiturate 1 (0.6) 3 (0.5) 3.07 (0.22 to 42.11)  
Benzodiazepine 12 (7.6) 25 (3.9) 0.88 (0.43 to 1.80)  
Histamine H-2 receptor antagonist 7 (4.4) 25 (3.9) 1.00 (0.39 to 2.54)  
Mood stabilizer 1 (0.6) 0 (0.0) inestimable  
Opiate 4 (2.5) 18 (2.8) 1.20 (0.37 to 3.87)  
Proton pump inhibitor 11 (6.9) 14 (2.2) 3.12 (1.24 to 7.85)  

Appendix

Codes used to identify community-acquired pneumonia.
Code Description
AyuKA00 KLEBSIELLA PNEUMONIAE/CAUSE/DISEASE CLASSIFD/OTH CHAPTERS
AyuK900 MYCOPLASMA PNEUMONIAE [PPLO]CAUSE/DIS CLASSIFD/OTH CHAPTR
Hyu0A00 OTHER BACTERIAL PNEUMONIA
Hyu0H00 OTHER PNEUMONIA, ORGANISM UNSPECIFIED
Hyu0900 PNEUMONIA DUE TO OTHER AEROBIC GRAM-NEGATIVE BACTERIA
Hyu0B00 PNEUMONIA DUE TO OTHER SPECIFIED INFECTIOUS ORGANISMS
Hyu0C00 PNEUMONIA IN BACTERIAL DISEASES CLASSIFIED ELSEWHERE
AyuK300 STREPTOCOC PNEUMON/CAUSE/DISEASE CLASSIFIED/OTH CHAPTERS
H530300 ABSCESS OF LUNG WITH PNEUMONIA
H470312 ASPIRATION PNEUMONIA DUE TO VOMIT
H28..00 ATYPICAL PNEUMONIA
H22z.00 BACTERIAL PNEUMONIA NOS
H261.00 BASAL PNEUMONIA DUE TO UNSPECIFIED ORGANISM
485 BRONCHOPNEUMONIA
H25..00 BRONCHOPNEUMONIA DUE TO UNSPECIFIED ORGANISM
H270.11 CHEST INFECTION - INFLUENZA WITH PNEUMONIA
H22..11 CHEST INFECTION - OTHER BACTERIAL PNEUMONIA
H26..11 CHEST INFECTION - PNEMONIA DUE TO UNSPECIFIED ORGANISM
H21..11 CHEST INFECTION - PNEUMOCOCCAL PNEUMONIA
H23..11 CHEST INFECTION - PNEUMONIA ORGANISM OS
H25..11 CHEST INFECTION - UNSPECIFIED BRONCHOPNEUMONIA
H24..11 CHEST INFECTION WITH INFECTIOUS DISEASE EC
H233.00 CHLAMYDIAL PNEUMONIA
H22y011 E.COLI PNEUMONIA
H540100 HYPOSTATIC BRONCHOPNEUMONIA
H540000 HYPOSTATIC PNEUMONIA
H56y100 INTERSTITIAL PNEUMONIA
A3BXB00 KLEBSIELLA PNEUMONIAE/CAUSE/DISEASE CLASSIFD/OTH CHAPTERS
H21..00 LOBAR (PNEUMOCOCCAL) PNEUMONIA
481 B LOBAR PNEUMONIA
H260.00 LOBAR PNEUMONIA DUE TO UNSPECIFIED ORGANISM
A3BXA00 MYCOPLASMA PNEUMONIAE [PPLO] CAUSE/DIS CLASSIFD/OTH CHAPTR
SP13100 OTHER ASPIRATION PNEUMONIA AS A COMPLICATION OF CARE
H22..00 OTHER BACTERIAL PNEUMONIA
H2y..00 OTHER SPECIFIED PNEUMONIA OR INFLUENZA
A3By400 PLEUROPNEUMONIA-LIKE ORGANISM (PPLO) INFECTION
486 PNEUMONIA
H22y200 PNEUMONIA – LEGIONELLA
486 AP PNEUMONIA ASPIRATION
483 AT PNEUMONIA ATYPICAL
481 BA PNEUMONIA BASAL
486 CA PNEUMONIA COLD AGGLUTININ POSITIVE
H22yz00 PNEUMONIA DUE TO BACTERIA NOS
H230.00 PNEUMONIA DUE TO EATON'S AGENT
H22y000 PNEUMONIA DUE TO ESCHERICHIA COLI
H222.11 PNEUMONIA DUE TO HAEMOPHILUS INFLUENZAE
H222.00 PNEUMONIA DUE TO HAEMOPHILUS INFLUENZAE
H220.00 PNEUMONIA DUE TO KLEBSIELLA PNEUMONIAE
H231.00 PNEUMONIA DUE TO MYCOPLASMA PNEUMONIAE
H22yX00 PNEUMONIA DUE TO OTHER AEROBIC GRAM-NEGATIVE BACTERIA
H22y.00 PNEUMONIA DUE TO OTHER SPECIFIED BACTERIA
H23..00 PNEUMONIA DUE TO OTHER SPECIFIED ORGANISMS
H232.00 PNEUMONIA DUE TO PLEUROPNEUMONIA LIKE ORGANISMS
H22y100 PNEUMONIA DUE TO PROTEUS
H221.00 PNEUMONIA DUE TO PSEUDOMONAS
H23z.00 PNEUMONIA DUE TO SPECIFIED ORGANISM NOS
H224.00 PNEUMONIA DUE TO STAPHYLOCOCCUS
H223.00 PNEUMONIA DUE TO STREPTOCOCCUS
H223000 PNEUMONIA DUE TO STREPTOCOCCUS, GROUP B
H26..00 PNEUMONIA DUE TO UNSPECIFIED ORGANISM
483 E PNEUMONIA EATON'S AGENT
514 HP PNEUMONIA HYPOSTATIC
4820K PNEUMONIA KLEBSIELLA
483 M PNEUMONIA MYCOPLASMAL
7789AP PNEUMONIA NEWBORN ASPIRATION
H2z..00 PNEUMONIA OR INFLUENZA NOS
481 A PNEUMONIA PNEUMOCOCCAL
483 AP PNEUMONIA PRIMARY ATYPICAL
4823 PNEUMONIA STAPHYLOCOCCAL
H24..00 PNEUMONIA WITH INFECTIOUS DISEASES EC
H24z.00 PNEUMONIA WITH INFECTIOUS DISEASES EC NOS
H24y.00 PNEUMONIA WITH OTHER INFECTIOUS DISEASES EC
H24yz00 PNEUMONIA WITH OTHER INFECTIOUS DISEASES EC NOS
H243.11 PNEUMONIA WITH PERTUSSIS
H24y400 PNEUMONIA WITH SALMONELLOSIS
H243.00 PNEUMONIA WITH WHOOPING COUGH
A022200 SALMONELLA PNEUMONIA
A3BX400 STREPTOCOC PNEUMON/CAUSE/DISEASE CLASSIFIED/OTH CHAPTERS
Codes used to identify community-acquired aspiration pneumonia or pneumonitis.
Code Description
Hyu4700 [X]PNEUMONITIS DUE TO INHALATION OF OTHER SOLIDS AND LIQUIDS
H470312 ASPIRATION PNEUMONIA DUE TO VOMIT
H47..11 ASPIRATION PNEUMONITIS
SP13100 OTHER ASPIRATION PNEUMONIA AS A COMPLICATION OF CARE
486 AP PNEUMONIA ASPIRATION
H470.00 PNEUMONITIS DUE TO INHALATION OF FOOD OR VOMITUS
H470z00 PNEUMONITIS DUE TO INHALATION OF FOOD OR VOMITUS NOS
H470100 PNEUMONITIS DUE TO INHALATION OF GASTRIC SECRETIONS
H47y.00 PNEUMONITIS DUE TO INHALATION OF OTHER SOLID OR LIQUID
H470000 PNEUMONITIS DUE TO INHALATION OF REGURGITATED FOOD
H47z.00 PNEUMONITIS DUE TO INHALATION OF SOLID OR LIQUID NOS [Same
H47yz00 PNEUMONITIS DUE TO INHALATION OF SOLID OR LIQUID NOS OK?]
H47..00 PNEUMONITIS DUE TO INHALATION OF SOLIDS OR LIQUIDS
H470300 PNEUMONITIS DUE TO INHALATION OF VOMITUS
H470311 VOMIT INHALATION PNEUMONITIS
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