2 Apr 2013: (2013) Correction: The Association between Histamine 2 Receptor Antagonist Use and Clostridium difficile Infection: A Systematic Review and Meta-analysis. PLoS ONE 8(4): 10.1371/annotation/56f8945c-33f6-45bf-87ce-dd512f7c25b0. doi: 10.1371/annotation/56f8945c-33f6-45bf-87ce-dd512f7c25b0 | View correction
Clostridium difficile infection (CDI) is a major health problem. Epidemiological evidence suggests that there is an association between acid suppression therapy and development of CDI.
We sought to systematically review the literature that examined the association between histamine 2 receptor antagonists (H2RAs) and CDI.
We searched Medline, Current Contents, Embase, ISI Web of Science and Elsevier Scopus from 1990 to 2012 for all analytical studies that examined the association between H2RAs and CDI.
Two authors independently reviewed the studies for eligibility.
Data about studies characteristics, adjusted effect estimates and quality were extracted.
Thirty-five observations from 33 eligible studies that included 201834 participants were analyzed. Studies were performed in 6 countries and nine of them were multicenter. Most studies did not specify the type or duration of H2RAs therapy. The pooled effect estimate was 1.44, 95% CI (1.22–1.7), I2 = 70.5%. This association was consistent across different subgroups (by study design and country) and there was no evidence of publication bias. The pooled effect estimate for high quality studies was 1.39 (1.15–1.68), I2 = 72.3%. Meta-regression analysis of 10 study-level variables did not identify sources of heterogeneity. In a speculative analysis, the number needed to harm (NNH) with H2RAs at 14 days after hospital admission in patients receiving antibiotics or not was 58, 95% CI (37, 115) and 425, 95% CI (267, 848), respectively. For the general population, the NNH at 1 year was 4549, 95% CI (2860, 9097).
In this rigorous systematic review and meta-analysis, we observed an association between H2RAs and CDI. The absolute risk of CDI associated with H2RAs is highest in hospitalized patients receiving antibiotics.
Citation: Tleyjeh IM, Abdulhak AAB, Riaz M, Garbati MA, Al-Tannir M, et al. (2013) The Association between Histamine 2 Receptor Antagonist Use and Clostridium difficile Infection: A Systematic Review and Meta-analysis. PLoS ONE 8(3): e56498. doi:10.1371/journal.pone.0056498
Editor: Adrian V. Hernandez, Universidad Peruana de Ciencias Aplicadas (UPC), Peru
Received: August 31, 2012; Accepted: January 10, 2013; Published: March 4, 2013
Copyright: © 2013 Tleyjeh et al. This is an open-access article distributed under the terms of the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original author and source are credited.
Funding: The authors have no support or funding to report.
Competing interests: The authors have declared that no competing interests exist.
Clostridium difficile infection (CDI) is considered a major health problem with a point prevalence of 13.1/1000 in-patient  and is increasing in incidence and mortality –. The CDI cost in the United States of America (USA) alone was conservatively estimated to exceed $1.1 billion annually . Risk factors associated with CDI acquisition are numerous and traditionally have included exposure to antibiotics, advanced age, comorbidities, enteral feeding, prolonged hospitalization, endoscopy and antineoplastic medications –.
The role of gastric acid suppression therapy has gained interest recently as a risk factor for CDI. Four recently published meta-analyses have suggested an association between gastric acid suppression therapy with proton pump inhibitors (PPI) and CDI –. The United States Food and Drug Administration (FDA) recently warned the public about a possible association between CDI and PPI use . However, to date; there is no systematic review dedicated to evaluate the potential association between histamine 2 receptors antagonists (H2RAs) use and risk of CDI.
H2RAs are popular over-the-counter (OTC) drugs worldwide . Off -label use of H2RAs and substitution for physician care were reported in 46 % and 34% of the adult consumer, respectively . Masking serious conditions, missed diagnosis, and the potential for inappropriate use by patients are concerns about OTC use of H2RAs . Nonetheless, the implications of OTC H2RAs use are not yet well defined.
Given the high prevalence of prescription use and OTC use of H2RAs and the increasing incidence and severity of CDI, we sought to systematically review the published literature that examined the association between H2RAs use and development of CDI following the MOOSE  and PRISMA  guidelines. We use the Grades of Recommendation, Assessment, Development and Evaluation (GRADE) framework  to interpret our findings.
The search strategy and subsequent literature searches were performed by a medical reference librarian (PJE) with 37 years of experience. The initial strategy was developed in Ovid MEDLINE (1990 through January 2012), using MeSH (Medical Subject Headings) controlled vocabulary, and then modified for Ovid EMBASE (1990 through January 2012). Primary terms were: enterocolitis, pseudomembranous/ AND the therapeutic agents of interest: explode omeprazole, explode proton pump inhibitors, anti-ulcer agents, and explode histamine H2 antagonists (Explode allows including all of the specific drugs, without having to use all of the various terms, synonyms, brands and generic names.) Articles were limited to randomized controlled trials, cohort studies, and or case-control studies. The same process was used with Ovid EMBASE with alterations as necessary to accommodate EMBASE's more granular subject headings. ISI Web of Science and Elsevier Scopus use text words: (difficile OR pseudomembranous OR pseudo-membranous) AND (omeprazole OR “proton pump” OR ranitidine OR h2 OR h-2 OR “acid suppression” OR antacid*)) AND (random* OR trial* OR blind* OR cohort* OR controlled OR prospective). Moreover, bibliographic references of all articles and previous meta-analyses were searched for eligible studies. We have designed the search strategy to capture any association between gastric acid suppression therapy and development of CDI.
There was no restriction to language. All results were downloaded into EndNote 7.0 (Thompson ISI Research soft, Philadelphia, Pennsylvania), a bibliographic database manager, and duplicate citations were identified and removed. Two authors (A.B.A. and F.A.) independently assessed the eligibility of identified studies.
To be included, a study had to: (1) be an analytical study; and (2) examine the association between H2RAs use and incidence of CDI in adult population.
A data collection form was developed and used to retrieve information on relevant features and results of pertinent studies. Two reviewers (A.B.A. and F.A.) independently extracted and recorded data in a predefined checklist. Disagreements among reviewers were discussed with two other reviewers (I.M.T. and M.A.A.), and agreement was reached by consensus. We collected adjusted effect estimates and 95% confidence intervals (CI) based on the multivariable regression model used in each study.
We used the Newcastle-Ottawa Quality Assessment Scale for cohort and case-control studies  which is intended to rate selection bias, comparability of the exposed and unexposed groups of each cohort, outcome assessment, and attrition bias. Two reviewers (M.A.G and F.A.) independently assessed the methodological quality of selected. Disagreement among reviewers was discussed with 2 other reviewers (I.M.T. and M.A.A.), and agreement was reached by consensus.
We used the GRADE framework to interpret our findings. The Cochrane Collaboration has adopted the principles of the GRADE system  for evaluating the quality of evidence for outcomes reported in systematic reviews.
For purposes of systematic reviews, the GRADE approach defines the quality of a body of evidence as the extent to which one can be confident that an estimate of effect or association is close to the quantity of specific interest. Quality of a body of evidence involves consideration of within-study risk of bias (methodological quality), directness of evidence, heterogeneity, precision of effect estimates and risk of publication bias.
The primary effect measures used in the meta-analysis were Odds Ratios (OR), Hazard Ratios (HR) and Relative Risks (RR) which were assumed to reasonably estimate the same association between CDI and H2RAs given the low incidence of CDI and thus were pooled together. Adjusted effect estimates were primarily used for this analysis. Unadjusted effect estimates were used as alternatives if studies did not pursue adjustment because of absence of association on univariate comparison.
Effect estimates from all included studies were pooled in a meta-analysis weighing individual studies according to their log-transformed inverse variance. The DerSimonian and Laird random effects model  was used to calculate the pooled effect estimates.
We extracted data on the proportion of CDI cases that were exposed to antibiotics from all studies that reported these data. We then performed a meta-analysis for the proportion on logit scale using random effects model weighing the individual studies according to their log-transformed inverse variance.
Homogeneity among studies was tested by means of Cochran's Q test and calculation of the variation across studies attributable to heterogeneity rather than chance (I2). The influence of a range of a-priori selected study-level and aggregated individual-level parameters on the observed effect estimate was investigated by means of meta-regressions. In these analyses, the log odds ratio from each study was regressed on the potential confounders in univariate and multivariate weighted linear regressions, weighted according to the inverse standard error and the residual between-study variance. Ten potential confounders were considered. Seven variables were categorical: design of the study (case-control vs. cohort), country of publication, setting (single center vs. multicenter), method of ascertainment of antibiotic use, method of effect measure (OR vs. RR/HR), effect estimate (adjusted vs. unadjusted) and quality of included studies (high score vs. low score). Three continuous variables were: the impact factor of the journal where the study was published, number of variables the effect measure was adjusted for and proportion of cases that were exposed to antibiotics.
The possible influence of publication bias was graphically assessed with the novel method of contour-enhanced funnel plot where log-transformed odds ratios were plotted against standard errors. This method examines whether any funnel plot asymmetry is likely to be due to publication bias compared with other underlying causes of funnel plot asymmetry. The contours help to indicate whether areas of the plot, where studies are perceived to be missing, are where studies would have statistically significant effect sizes or not and thus decrease or increase the evidence that the asymmetry is due to publication bias. The presence of funnel plot asymmetry was also assessed using Egger's test .
Finally, the possible influence of unknown confounders (residual confounding) was investigated with a rule-out approach described by Schneeweiss . This approach stipulates the influence of a hypothetical confounder and determines what characteristics this confounder must have to fully account for the observed association between use of H2RAs and occurrence of CDI. The hypothetical confounder is characterized by its association to H2RAs use (OREC, odds ratio of exposure to the confounder) and its association to the outcome (RRCO, relative risk of outcome in individuals exposed to the confounder vs. non-exposed). For this analysis, the absolute risk in the pooled non-exposed group was used for conversion of odds ratio to relative risk using the method described by Zhang and Yu . Separate analyses were performed to demonstrate what levels of OREC and RRCO would be required to fully explain the observed association between H2RAs and CDI for different hypothetical prevalence of the unknown confounder (i.e. PC = 0.2, PC = 0.4) before and after adjustment for publication bias as described above.
In all analyses, results associated with p-values <0.05 (two-sided test) were considered statistically significant. All statistical analyses were performed using Stata version 12 statistical software (StataCorp, College Station, Texas).
The search yielded 27 eligible studies after excluding 260 citations. Six more studies were retrieved from recent review articles and added to the total eligible studies. Kutty  et al and Jayatilaka  et al, each reported 2 different observations for different participants. Thus, a total of 33 articles met our inclusion criteria representing 35 observations that included 201834 participants. There was excellent agreement for the inclusion of the studies, data abstraction and quality assessment between the reviewers (kappa statistic being 1.0, 1.0 and 0.91 respectively).
The study selection process is illustrated in Figure 1 and the main characteristics of the included studies are summarized in Table 1. Twenty-four case control studies –, , –, – and 11 cohort studies –, –,  reported data on both community-acquired and hospital-acquired CDI (8 observations were from community-acquired CDI, 23 from hospital-acquired CDI and 4 representing both type of CDI). Six studies , , , , ,  were from multiple centers; two from UK general practice research database , , and the remaining were from single centers. The included studies were performed in 6 countries (17 studies from USA, 9 from Canada, 6 from United Kingdom, 1 from Netherlands, 1 from Israel, and one from Korea). Most studies did not specify the type or duration of therapy with H2RAs. Tables 2 and 3 summarized the case ascertainment, control or non-exposed group selection method for case control and cohort studies, respectively. Among all citations, seventeen studies reported the proportion of cases exposed to antibiotics. Eight studies used antibiotics exposure as inclusion criteria. Three studies did not provide either the absolute number of exposed or unexposed groups thus were not included in this pooled proportion analysis.
Figure 1. Flow diagram of eligible studies.doi:10.1371/journal.pone.0056498.g001
Table 1. Characteristics of the included studies.doi:10.1371/journal.pone.0056498.t001
Table 2. The Association between H2RAs use and development of Clostridium difficile infection from case-control studies.doi:10.1371/journal.pone.0056498.t002
Table 3. The Association between H2RAs use and development of Clostridium difficile infection from cohort studies.doi:10.1371/journal.pone.0056498.t003
Quality assessment of all included studies was done using the validated Newcastle-Ottawa Quality Assessment Scale  for cohort and case control studies (Tables 4 and 5). Included studies were scored based on the sum number of the stars given to each study. Among case-control studies, Loo et al 2011, Manges et al 2010, McFarland et al 2007, Modena et al 2005 and Dial et al 2008 scored the lowest. While Beaulieu et al 2005 scored the lowest among cohort studies. Most studies were of good quality with no evidence of selection bias, and with good comparability of the exposed and unexposed groups of each cohort, and outcome assessment.
Table 4. Modified Newcastle-Ottawa quality assessment scale for case-control studies included in the meta-analysis.doi:10.1371/journal.pone.0056498.t004
Table 5. Modified Newcastle-Ottawa Quality Assessment Scale for Cohort studies included in the Meta-analysisdoi:10.1371/journal.pone.0056498.t005
Thirty-five observations from 33 eligible studies were pooled using a random effect model meta-analysis. We excluded the study by Jenkins et al. as an outlier due to its large standard error. The pooled effect estimate was 1.44, 95% CI (1.22–1.7), I2 = 70.5%. The pooled effect estimate for high quality studies was 1.39 (1.15–1.68), I2 = 72.3%.
Although the heterogeneity between the analyzed studies was moderate, the majority of studies pointed towards a positive association. Figure 2 shows the forest plot and the pooled effect estimate for all studies stratified by country. Table 6 summarizes the pooled estimates and associated heterogeneity across different subgroups. The pooled proportion of CDI cases that were exposed to antibiotics was 0.81, 95% CI (0.65–0.91) as shown in Figure 3.
Figure 2. Forest plot-random effect model meta-analysis of the association between CDI and H2RAs based on 35 observations stratified by country.
Error bars indicate confidence interval.doi:10.1371/journal.pone.0056498.g002
Figure 3. Forest plot of the pooled proportion of Clostridium difficile cases that were exposed to antibiotics.doi:10.1371/journal.pone.0056498.g003
Table 6. Influence of study type and country on the pooled effect estimate and its associated heterogeneity.doi:10.1371/journal.pone.0056498.t006
The influence of a range of a-priori selected study-level and aggregated individual-level parameters on the observed effect estimate was investigated by means of meta-regressions. Table 7 summarizes the meta-regression analyses for all 35 results. Heterogeneity could not be explained by any of the 10 considered variables.
Table 7. Meta-regression analysis to explore sources of heterogeneity.doi:10.1371/journal.pone.0056498.t007
Figure 4 displays the contour enhanced funnel plot which showed no evidence of publication bias. This was confirmed by the Egger's test (P = 0.905).
Figure 4. Contour-enhanced funnel plot
of the association between the estimated effect size and its standard error in all studies comparing those exposed and unexposed to H2RA displays areas of statistical significance on a funnel plot. Contours represent conventional “milestone” levels of statistical significance (e.g., <0.01, <0.05, <0.1). This funnel plot is symmetrical as it is not missing studies in the white area excluding the possibility of publication bias (Egger's test, p = 0.905).doi:10.1371/journal.pone.0056498.g004
The results of the residual confounding analysis are presented in Figure 5. Panel A refers to a confounder with a prevalence of 0.20; at this prevalence level, a strong confounder causing a two-fold increased risk of CDI would have to be severely imbalanced between H2 blockers users and non users (OREC = 8.87) in order to fully account for the observed adjusted RR of 1.40. For a very common confounder with a prevalence of 0.40, stronger associations with acid-suppression use and/or CDI would be needed to explain the observed association between acid-suppression use and CDI. At this prevalence level, the confounder would have to be both imbalanced (OREC = 5.87) and increase the CDI risk (2.5-fold) to account for the observed OR, after taking publication bias into account.
Figure 5. Influence of a hypothetical dichotomous confounder present in 20% (panel A) and 40% (panel B) of the study population, unaccounted for in prior adjustments performed in individual studies.
The graphs depict what combinations of OREC and RR would be necessary for the confounder to fully account for the observed association between H2RA use and CDI acquisition. Abbreviations: OREC, odds ratio of exposure to the confounder in H2RA non-users vs. H2RA users; RRCD, relative risk of CDAD in individuals exposed to the confounder vs. non-exposed.doi:10.1371/journal.pone.0056498.g005
Number needed to harm
The number needed to harm (NNH) was estimated by using the pooled OR from the meta-analysis . A recent large prospective hospital cohort  reported the incidence of CDI at 14 days after hospital admission in patients receiving antibiotics or not: which was 42/1,000 and 5.4/1000, respectively. Based on these reported baseline risks, the number needed to harm (NNH) was 58, 95% CI (37, 115) and 425, 95% CI (267, 848), respectively. For the general population, the NNH at 1 year was 4549, 95% CI (2860, 9097) at 1 year, based on a baseline incidence of CDI of 48/100,000 person-years .
In this rigorously conducted systematic review and meta-analysis, we observed an association between H2RAs use and development of CDI. Using the GRADE framework, the evidence supporting this association is considered of moderate quality. Although evidence from observational studies is considered of weak quality, we have ruled out a strong effect of an unmeasured confounder and, therefore, have upgraded its quality to moderate evidence in favor of this association.
The absolute risk of CDI was highest in hospitalized patients receiving antibiotics with an estimated NNH of 58 at 2 weeks. In contrast, the risk was very low (4549) in the general population. We also observed that, on average, 19% of CDI cases had not been recently exposed to antibiotics.
These findings add to previous subgroup analyses of a limited number of H2RA studies performed in a recent systematic review of the association between PPI and CDI. In this review, Kwok  et al conducted a subgroup analysis of 15 H2RA studies and reported a pooled effect estimate of 1.50, 95% CI (1.23–1.83). Similarly, Leonard et al  reported in 2007 an analysis based on 12 studies that showed H2RAs use was also associated with risk of CDI with a pooled OR 1.40, 95% CI (0.85–2.29).
The pathogenic mechanisms operative in H2RAs therapy causing an increased risk of CDI acquisition are unclear, because gastric acid does not kill gastric C. difficile spores. One potential explanation for the association between CDI and gastric acid suppression therapies could be that the vegetative form of C. difficile, which is killed by acid, plays a role in pathogenesis. Vegetative forms survive on surfaces and could be ingested by patients . Survival of acid-sensitive vegetative forms in the stomach could be facilitated by two primary factors: (1) suppression of gastric acid production by acid-suppressive medications; and (2) presence of bile salts in gastric contents of patients on acid-suppressive therapy. Bile salts, which are mainly found in the small intestine, are present in gastric contents, particularly among patients with gastro-esophageal reflux disease (GERD).
The extent of gastric acid suppression could play an important role in potentiating the risk of infection. Kwok  et at compared the risk of CDI with gastric acid suppression from 15 studies that reported on estimates of both PPI and H2RAs independently on their sample of participants and found that PPI is associated with higher risk of infection in comparison to H2RAs though both increase the risk.
Our findings have global implications both on the inappropriate use of acid-suppression therapy and on the increasing incidence of CDI.
Given the relatively low NNH (58 patients) needed to cause a case of CDI in hospitalized patients receiving antibiotics it becomes necessary to judiciously use H2RAs in these patients. In addition, reducing the inappropriate use of acid-suppression medications in this patient population could lead to a significant reduction in the incidence of CDI.
On the other hand, our findings are re-assuring to the public that H2RAs use in the general population as over-the-counter medications do not pose significant CDI risk and is associated with a high NNH.
Our study has several important strengths. This review is the first systematic evaluation dedicated to examine the association between H2RAs and risk of CDI. It includes a comprehensive, up-to-date literature search and formal assessment of the methodological quality of pertinent studies with the largest number of relevant studies as compared to previous reviews 11,61. In addition, our pooled estimates are based on multivariate ORs of studies adjusting for several important CDI risk factors. We also performed subgroup analyses and sensitivity analyses that confirmed the robustness of our main results. There was no statistical evidence of publication bias and the effect of residual confounding on the observed association was examined. Finally, the NNH in different risk groups was calculated to aid physicians and patients in making a decision to use H2RA or not.
Our review has certain limitations. There was moderate between-study heterogeneity; however, this is often the case in meta-analyses of large observational studies –. Moreover the majority of studies pointed towards a positive association. There was virtually no qualitative heterogeneity, and subgroup and sensitivity analyses showed results consistent with the main analysis. There are many patient level parameters which may have led to substantial heterogeneity. Nevertheless, investigating these variables is only possible with individual patient data meta-analysis.
In this rigorous systematic review and meta-analysis, we observed an association between H2RAs and CDI. The absolute risk of CDI associated with H2RAs was highest in hospitalized patients receiving antibiotics. On the other hand, our findings are re-assuring that H2RAs use in the general population as over-the-counter medications do not pose a significant CDI risk.
PRISMA 2009 flow diagram.
Conceived and designed the experiments: IMT ABA AS MR LMB. Analyzed the data: IMT AS MR ABA. Wrote the paper: IMT ABA AS MR FAA MAA MAT MAG ARK PJE LMB.
- 1. Jarvis WR, Schlosser J, Jarvis AA, Chinn RY (2009) National point prevalence of Clostridium difficile in US health care facility inpatients, 2008. Am J Infect Control 37: 263–270. doi: 10.1016/j.ajic.2009.01.001
- 2. Archibald LK, Banerjee SN, Jarvis WR (2004) Secular trends in hospital-acquired Clostridium difficile disease in the United States, 1987–2001. J Infect Dis 189: 1585–1589. doi: 10.1086/383045
- 3. McDonald LC, Owings M, Jernigan DB (2006) Clostridium difficile infection in Patients discharged from US short-stay hospitals, 1996–2003. Emerg Infect Dis 12: 409–415. doi: 10.3201/eid1205.051064
- 4. Elixhauser A, Jhung M. Clostridium difficile-associated disease in US hospitals, 1993–2005. Statistical Brief #50: Clostridium difficile-Associated Disease in U.S. Hospitals, 1993–2005.Available at: http://www.hcupus.ahrq.gov/reports/statbriefs/sb50.jsp. Last accessed Oct 21/2012.
- 5. Redelings MD, Sorvillo F, Mascola L (2007) Increase in Clostridium difficile-related mortality rates, United States, 1999–2004. Emerg Infect Dis 13: 1417–1419. doi: 10.3201/eid1309.061116
- 6. Kyne L, Hamel MB, Polavaram R, Kelly CP (2002) Health care costs and mortality associated with nosocomial diarrhea due to Clostridium difficile. Clin Infect Dis 34: 346–353. doi: 10.1086/338260
- 7. Schuller I, Saha V, Lin L, Kingston J, Eden T, et al. (1995) Investigation and Management of Clostridium difficile colonisation in a paediatric oncology unit. Arch Dis Child 72: 219–222. doi: 10.1136/adc.72.3.219
- 8. Emoto M, Kawarabayashi T, Hachisuga MD, Eguchi F, Shirakawa K (1996) Clostridium difficile colitis associated with cisplatin-based chemotherapy in ovarian cancer patients.Gynecol Oncol. 61: 369–372. doi: 10.1006/gyno.1996.0158
- 9. Bliss DZ, Johnson S, Savik K, Clabots CR, Willard K, et al. (1998) Acquisition of Clostridium difficile and Clostridium difficile-associated diarrhea in hospitalized Patients receiving tube feeding. Ann Intern Med 129: 1012–1019. doi: 10.7326/0003-4819-129-12-199812150-00004
- 10. Brown E, Talbot GH, Axelrod P, Provencher M, Hoegg C (1990) Risk factors for Clostridium difficile toxin-associated diarrhea. Infect Control Hosp Epidemiol 11: 283–290. doi: 10.1086/646173
- 11. Kwok CS, Arthur AK, Anibueze CI, Singh S, Cavallazzi R, et al. (2012) Risk of Clostridium difficile infection with acid suppressing drugs and antibiotics: meta-analysis. Am J Gastroenterol 107: 1011–1019.
- 12. Deshpande A, Pant C, Pasupuleti V, Rolston DD, Jain A, et al. (2012) Association between proton pump inhibitor therapy and Clostridium difficile infection in a meta-analysis. Clin Gastroenterol Hepatol 10: 225–233. doi: 10.1016/j.cgh.2011.09.030
- 13. Bavishi C, Dupont HL (2011) Systematic review: the use of proton pump inhibitors and increased susceptibility to enteric infection. Aliment Pharmacol Ther 34: 1269–1281. doi: 10.1111/j.1365-2036.2011.04874.x
- 14. Tleyjeh IM, Bin Abdulhak AA, Riaz M, Alasmari FA, Garbati MA, et al. (2012) Association between Proton Pump Inhibitor Therapy and Clostridium difficile Infection: A Contemporary Systematic Review and Meta-Analysis. PLoS ONE 7(12): e50836 doi:10.1371/journal.pone.0050836.
- 15. U.S food and drug administration. Proton Pump Inhibitors (PPIs) – Drug Safety Communication: Clostridium difficile-Associated Diarrhea (CDAD) Can be Associated With Stomach Acid Drugs. Available: http://www.fda.gov/Safety/MedWatch/SafetyInformation/SafetyAlertsforHumanMedicalProducts/ucm290838.htm. Accessed May, 31, 2012.
- 16. Shi CW, Gralnek IM, Dulai GS, Towfigh A, Asch S (2004) Consumer usage patterns of nonprescription histamine2-receptor antagonists. Am J Gastroenterol 99 (4): 606–10.
- 17. Erwin J, Britten N, Jones R (1997) General practitioners' views on the over-the-counter availability of H2-antagonists. Br J Gen Pract 47: 99–102.
- 18. Stroup DF, Berlin JA, Morton SC, Olkin I, Williamson GD, et al. (2000) Meta-analysis of observational studies in epidemiology: a proposal for reporting. Meta-analysis Of Observational Studies in Epidemiology (MOOSE) group. JAMA 283: 2008–2012. doi: 10.1001/jama.283.15.2008
- 19. Liberati A, Altman DG, Tetzlaff J, Mulrow C, Gøtzsche PC, et al. (2009) The PRISMA Statement for Reporting Systematic Reviews and Meta-Analyses of Studies That Evaluate Health Care Interventions: Explanation and Elaboration. PLoS Med 6(7): e1000100. doi: 10.1371/journal.pmed.1000100
- 20. Guyatt GH, Oxman AD, Vist GE, Kunz R, Falck-Ytter Y, et al. (2008) GRADE: an emerging consensus on rating quality of evidence and strength of recommendations. BMJ 336: 924–926. doi: 10.1136/bmj.39489.470347.ad
- 21. Wells G, Shea B, O'Connell D, et al. The Newcastle- Ottawa scale (NOS) for assessing the quality of non-randomized studies in meta-analysis. http://www.ohri.ca/programs/clinical_epidemiology/oxford.asp. Last accessed May31.2012.
- 22. DerSimonian R, Laird N (1986) Meta-analysis in clinical trials. Control Clin Trials 7: 177–188. doi: 10.1016/0197-2456(86)90046-2
- 23. Egger M, Davey Smith G, Schneider M, Minder C (1997) Bias in meta-analysis detected by a simple, graphical test. BMJ 315: 629–634. doi: 10.1136/bmj.315.7109.629
- 24. Schneeweiss S (2006) Sensitivity analysis and external adjustment for unmeasured confounders in epidemiologic database studies of therapeutics. Pharmacoepidemiol Drug Saf 15: 291–303. doi: 10.1002/pds.1200
- 25. Zhang J, Yu KF (1998) What's the relative risk? A method of correcting the odds ratio in cohort studies of common outcomes. JAMA 280: 1690–1691. doi: 10.1001/jama.280.19.1690
- 26. Kutty PK, Woods CW, Sena AC, Benoit SR, Naggie S, et al.. (2010) Risk factors for and estimated incidence of community-associated Clostridium difficile infection, North Carolina, USA. Emerg Infect Dis 16: 197 204.
- 27. Jayatilaka S, Shakov R, Eddi R, Bakaj G, Baddoura WJ, et al. (2007) Clostridium difficile infection in an urban medical center: five-year analysis of infection rates among adult admissions and association with the use of proton pump inhibitors. Ann Clin Lab Sci 37: 241–247.
- 28. Nath SK, Salama S, Persaud D, Thornley JH, Smith I, et al. (1994) Drug risk factors associated with a sustained outbreak of Clostridium difficile diarrhea in a teaching hospital. Can J Infect Dis 5: 270–275.
- 29. Shah S, Lewis A, Leopold D, Dunstan F, Woodhouse K (2000) Gastric acid suppression does not promote clostridial diarrhoea in the elderly. QJM 93: 175–181. doi: 10.1093/qjmed/93.3.175
- 30. Dial S, Delaney JA, Barkun AN, Suissa S (2005) Use of gastric acid-suppressive agents and the risk of community-acquired Clostridium difficile-associated disease. JAMA 294: 2989–2995. doi: 10.1001/jama.294.23.2989
- 31. Debast SB, Vaessen N, Choudry A, Wiegers-Ligtvoet EA, van den Berg RJ, et al. (2009) Successful combat of an outbreak due to Clostridium difficile PCR ribotype 027 and recognition of specific risk factors. Clin Microbiol Infect 15: 427–434. doi: 10.1111/j.1469-0691.2009.02713.x
- 32. Lowe DO, Mamdani MM, Kopp A, Low DE, Juurlink DN (2006) Proton pump inhibitors and hospitalization for Clostridium difficile-associated disease: a population-based study. Clin Infect Dis 43: 1272–1276. doi: 10.1086/508453
- 33. Dial S, Delaney JA, Schneider V, Suissa S (2006) Proton pump inhibitor use and risk of community acquired Clostridium difficile-associated disease defined by prescription for oral vancomycin therapy.CMAJ. 175: 745–748. doi: 10.1503/cmaj.060284
- 34. Aseeri M, Schroeder T, Kramer J, Zackula R (2008) Gastric acid suppression by proton pump inhibitors as a risk factor for Clostridium difficile-associated diarrhea in hospitalized patients. Am J Gastroenterol 103: 2308–2313.
- 35. Dubberke ER, Reske KA, Olsen MA, McMullen KM, Mayfield JL, et al. (2007) Evaluation of Clostridium difficile-associated disease pressure as a risk factor for C difficile-associated disease. Arch Intern Med (167) 1092–1097. doi: 10.1001/archinte.167.10.1092
- 36. Loo VG, Poirier L, Miller MA, Oughton M, Libman MD, et al. (2005) A predominantly clonal multi-institutional outbreak of Clostridium difficile-associated diarrhea with high morbidity and mortality. N Engl J Med 353: 2442–2449. doi: 10.1056/nejmoa051639
- 37. Sundram F, Guyot A, Carboo I, Green S, Lilaonitkul M, et al. (2009) Clostridium difficile ribotypes 027 and 106: clinical outcomes and risk factors. J Hosp Infect 72: 111–118. doi: 10.1016/j.jhin.2009.02.020
- 38. Howell MD, Novack V, Grgurich P, Soulliard D, Novack L, et al. (2010) Iatrogenic gastric acid suppression and the risk of nosocomial Clostridium difficile infection. Arch Intern Med 170: 784–790. doi: 10.1001/archinternmed.2010.89
- 39. Dalton BR, Lye-Maccannell T, Henderson EA, Maccannell DR, Louie TJ (2009) Proton pump inhibitors increase significantly the risk of Clostridium difficile infection in a low-endemicity, non-outbreak hospital setting. Aliment Pharmacol Ther 29: 626–634. doi: 10.1111/j.1365-2036.2008.03924.x
- 40. Dubberke ER, Reske KA, Yan Y, Olsen MA, McDonald LC, et al. (2007) Clostridium difficile – associated disease in a setting of endemicity: identification of novel risk factors. Clin Infect Dis 45: 1543–1549. doi: 10.1086/523582
- 41. Pepin J, Saheb N, Coulombe MA, Alary ME, Corriveau MP, et al. (2005) Emergence of fluoroquinolones as the predominant risk factor for Clostridium difficile-associated diarrhea: a cohort study during an epidemic in Quebec. Clin Infect Dis 41: 1254–1260. doi: 10.1086/496986
- 42. Beaulieu M, Williamson D, Pichette G, Lachaine J (2007) Risk of Clostridium difficile-associated disease among patients receiving proton-pump inhibitors in a Quebec medical intensive care unit. Infect Control Hosp Epidemiol 28: 1305–1307. doi: 10.1086/521664
- 43. Peled N, Pitlik S, Samra Z, Kazakov A, Bloch Y, et al. (2007) Predicting Clostridium difficile toxin in hospitalized patients with antibiotic-associated diarrhea. Infect Control Hosp Epidemiol 28: 377–381. doi: 10.1086/513723
- 44. Dial S, Alrasadi K, Manoukian C, Huang A, Menzies D (2004) Risk of Clostridium difficile diarrhea among hospital inpatients prescribed proton pump inhibitors: cohort and case-control studies. CMAJ 171: 33–38. doi: 10.1503/cmaj.1040876
- 45. Novell MJ, Morreale CA (2010) The relationship between inpatient fluoroquinolone use and Clostridium difficile-associated diarrhea. Ann Pharmacother : 826–831.
- 46. Netland PJ, Brochardt SM, Koo JM, Lo TS, Krenz T (2011) A Retrospective Analysis of Risk factors and Therapeutic Outcomes for Clostridium difficile Infection. Hosp Pham 46(5): 336–340. doi: 10.1310/hpj4605-336
- 47. Jung KS, Park JJ, Chon YE, Jung ES, Lee HJ, et al. (2010) Risk Factors for Treatment Failure and Recurrence after Metronidazole Treatment for Clostridium difficile-associated Diarrhea. Gut Liver 4: 332–337. doi: 10.5009/gnl.2010.4.3.332
- 48. Loo VG, Bourgault AM, Poirier L, Lamothe F, Michaud S, et al. (2011) Host and pathogen factors for Clostridium difficile infection and colonization. N Engl J Med 365: 1693–1703. doi: 10.1056/nejmoa1012413
- 49. Manges AR, Labbe A, Loo VG, Atherton JK, Behr MA, et al. (2010) Comparative metagenomic study of alterations to the intestinal microbiota and risk of nosocomial Clostridum difficile-associated disease. J Infect Dis 202: 1877–1884. doi: 10.1086/657319
- 50. Kuntz JL, Chrischilles EA, Pendergast JF, Herwaldt LA, Polgreen PM (2011) Incidence of and risk factors for community-associated Clostridium difficile infection: a nested case-control study. BMC Infect Dis 11: 194. doi: 10.1186/1471-2334-11-194
- 51. Naggie S, Miller BA, Zuzak KB, Pence BW, Mayo AJ, et al.. (2011) A case control study of community associated Clostridium difficile infection: no role for proton pump inhibitors. Am J Med 124: 276 e271–277.
- 52. Stevens V, Dumyati G, Brown J, Wijngaarden E (2011) Differential risk of Clostridium difficile infection with proton pump inhibitor use by level of antibiotic exposure. Pharmacoepidemiol Drug Saf 20: 1035–1042. doi: 10.1002/pds.2198
- 53. Dial S, Kezouh A, Dascal A, Barkun A, Suissa S (2008) Patterns of antibiotic use and risk of hospital admission because of Clostridium difficile infection. CMAJ 179: 767–772. doi: 10.1503/cmaj.071812
- 54. McFarland LV, Clarridge JE, Beneda HW, Raugi GJ (2007) Fluoroquinolone use and risk factors for Clostridium difficile-associated disease within a Veterans Administration health care system. Clin Infect Dis 45: 1141–1151. doi: 10.1086/522187
- 55. Kazakova SV, Ware K, Baughman B, Bilukha O, Paradis A, et al. (2006) A hospital outbreak of diarrhea due to an emerging epidemic strain of Clostridium difficile. Arch Intern Med 166: 2518–2524. doi: 10.1001/archinte.166.22.2518
- 56. Modena S, Bearelly D, Swartz K, Friedenberg FK (2005) Clostridium difficile among hospitalized patients receiving antibiotics: a case-control study. Infect Control Hosp Epidemiol 26: 685–690. doi: 10.1086/502603
- 57. Muto CA, Pokrywka M, Shutt K, Mendelsohn AB, Nouri K, et al. (2005) A large outbreak of Clostridium difficile-associated disease with an unexpected proportion of deaths and colectomies at a teaching hospital following increased fluoroquinolone use. Infect Control Hosp Epidemiol 26: 273–280. doi: 10.1086/502539
- 58. Yip C, Loeb M, Salama S, Moss L, Olde J (2001) Quinolone use as a risk factor for nosocomial Clostridium difficile-associated diarrhea. Infect Control Hosp Epidemiol 22: 572–575. doi: 10.1086/501954
- 59. Cates CJ (2002) Simpson's paradox and calculation of number needed to treat from meta-analysis. BMC Med Res Methodol 2: 1.
- 60. Khanna S, Pardi DS, Aronson SL, Kammer PP, Orenstein R, et al. (2012) The epidemiology of community-acquired Clostridium difficile infection: a population based study. Am J Gastroenterol 107: 89–95.
- 61. Leonard J, Marshall JK, Moayyedi P (2007) Systematic review of the risk of enteric infection in patients taking acid suppression. Am J Gastroenterol 102: 2047–2056.
- 62. Jump RL, Pultz MJ, Donskey CJ (2007) Vegetative Clostridium difficile survives in room air on moist surfaces and in gastric contents with reduced acidity: a potential mechanism to explain the association between proton pump inhibitors and C. difficile associated diarrhea? Antimicrob Agents Chemother 51: 2883–2887. doi: 10.1128/aac.01443-06
- 63. Coory MD (2010) Comment on: Heterogeneity in meta-analysis should be expected and appropriately quantified. Int J Epidemiol 39: 932; author reply 933.
- 64. Higgins JP (2008) Commentary: Heterogeneity in meta-analysis should be expected and appropriately quantified. Int J Epidemiol 37: 1158–1160. doi: 10.1093/ije/dyn204
- 65. Higgins JP, Thompson SG, Deeks JJ, Altman DG (2003) Measuring inconsistency in meta analyses. BMJ 327: 557–560. doi: 10.1136/bmj.327.7414.557