Results The adverse event rate among diclofenac initiators increased by 50% compared with non-initiators (incidence rate ratio 1.5, 95% confidence interval 1.4 to 1.7), 20% compared with paracetamol or ibuprofen initiators (both 1.2, 1.1 to 1.3), and 30% compared with naproxen initiators (1.3, 1.1 to 1.5). The event rate for diclofenac initiators increased for each component of the combined endpoint (1.2 (1.1 to 1.4) for atrial fibrillation/flutter, 1.6 (1.3 to 2.0) for ischaemic stroke, 1.7 (1.4 to 2.0) for heart failure, 1.9 (1.6 to 2.2) for myocardial infarction, and 1.7 (1.4 to 2.1) for cardiac death) as well as for low doses of diclofenac, compared with non-initiators. Although the relative risk of major adverse cardiovascular events was highest in individuals with low or moderate baseline risk (that is, diabetes mellitus), the absolute risk was highest in individuals with high baseline risk (that is, previous myocardial infarction or heart failure). Diclofenac initiation also increased the risk of upper gastrointestinal bleeding at 30 days, by approximately 4.5-fold compared with no initiation, 2.5-fold compared with initiation of ibuprofen or paracetamol, and to a similar extent as naproxen initiation.

Main outcome measures Cox proportional hazards regression was used to compute the intention to treat hazard ratio (as a measure of the incidence rate ratio) of major adverse cardiovascular events within 30 days of initiation.

Participants Individuals eligible for inclusion were all adults without malignancy; schizophrenia; dementia; or cardiovascular, kidney, liver, or ulcer diseases (that is, with low baseline risk). The study included 1 370 832 diclofenac initiators, 3 878 454 ibuprofen initiators, 291 490 naproxen initiators, 764 781 healthcare seeking paracetamol initiators matched by propensity score, and 1 303 209 healthcare seeking non-initiators also matched by propensity score.

Diclofenac is the most frequently used NSAID in low, middle, and high income countries, and is available over the counter in most countries; 5 therefore, its cardiovascular risk profile is of major clinical and public health importance. As a consequence, the European Medicines Agency has again called for a safety assessment of diclofenac. 6 In response, we conducted a series of cohort studies, each mimicking the strict design criteria of a clinical trial (a so-called emulated trial design), to compare rates of major adverse cardiovascular events among diclofenac initiators with rates among non-initiators or initiators of active comparator drugs.

The cardiovascular risks of non-aspirin, non-steroidal anti-inflammatory drugs (NSAIDs) remain a major safety concern after rofecoxib’s thromboembolic properties were revealed. 1 Diclofenac is a traditional non-steroidal anti-inflammatory drug (NSAID) with cyclo-oxygenase-2 (COX 2) selectivity similar to COX 2 inhibitors, 2 but its cardiovascular risks compared with those of other traditional NSAIDs have never been examined in a randomised controlled trial. 3 Current concerns about these risks, as stated by the European Society of Cardiology, 4 now make such a trial unethical to conduct.

This research was done without patient involvement. Patients were not invited to comment on the study design and were not consulted to develop patient relevant outcomes or interpret the results. Patients were not invited to contribute to the writing or editing of this document for readability or accuracy.

Use a rule-out approach 19 to estimate how strongly a single unmeasured binary confounder would need to be associated with use of diclofenac and major adverse cardiovascular events to fully explain our findings.

Change the cutoff limit for low dose diclofenac (from <100 mg to <75 mg and <50 mg tablets), to examine the effect of dose definitions, as high dose diclofenac (150 mg/day) has accounted for almost all outcomes in previous trials 3

Censor patients on redemption of a prescription for an NSAID other than the active comparator drug received at baseline, to examine the potential impact of crossover

In addition to our primary low risk population (defined by eligibility criteria), we repeated the sampling and analyses for patients with diabetes mellitus (that is, at moderate cardiovascular risk at baseline) and for patients with previous myocardial infarction or heart failure (that is, at high cardiovascular risk at baseline). In the high risk group, cardiovascular drug use within one year was omitted as an exclusion criterion. To facilitate the interpretation of the relative effect estimates, we also calculated adjusted incidence rate differences according to baseline cardiovascular risk. Finally, we stratified the study population by age (<65, 65-79, or ≥80 years), sex, calendar period (1996-2002, 2003-09, and 2010-16), and diclofenac dose (low dose (<100 mg) v high dose (100 mg) tablets).

We estimated an observational analogue of the intention to treat hazard ratio, as a measure of the incidence rate ratio, by fitting a Cox proportional hazards model, using time since start of follow-up as the time scale and a time independent covariate for treatment assignment. We pooled data from all trials into one model and included each trial as a stratum in the regression (using values from 1 to 252). The covariate values for each “trial” were based on the data most recently recorded at the start of the respective trial. Because individuals could participate in more than one of these trials, we used a robust variance estimator to estimate conservative 95% confidence intervals. 18 In the active NSAID comparator models, we adjusted for the baseline covariates on sex, age, year, comorbidity, and drug treatment use. Adjustment was used rather than propensity score matching to approximate a trial setting.

We characterised the study population by age, sex, comorbidity, and drug treatment use at baseline. We compared the distribution of baseline covariates in the propensity score matched samples using the standardised difference 16 and illustrated graphically the propensity score distribution before and after matching. Comorbidity was based on the complete five year inpatient and outpatient medical history in the Danish National Patient Registry (both primary and secondary diagnoses). Drug treatment use was defined as a redeemed prescription within 90 days before enrolment. To increase the completeness of diabetes, chronic obstructive pulmonary disease, and hypertension ascertainment, we also searched the Danish National Prescription Registry for any previous prescription redemption of diabetic, respiratory, or antihypertensive drugs. We defined hypertension as a hospital diagnosis or redemption of at least two prescriptions for antihypertensive drug classes within 90 days before enrolment. 17 All registry codes are provided in eTable 2.

The primary endpoint—major adverse cardiovascular events—was a composite of non-fatal events 10 and cardiac death. 8 Non-fatal events were defined as first time inpatient diagnoses of atrial fibrillation or flutter, ischaemic stroke, heart failure, and myocardial infarction. 10 For atrial fibrillation or flutter, we also included first time outpatient diagnoses. Cardiac death was defined as death from any cardiac cause. Secondary endpoints included all the individual components of major adverse cardiovascular events. Finally, we stratified cardiac death according to underlying causes.

Exclusion criteria were based on all information recorded in the Danish National Patient Registry (within five years) and Danish National Prescription Registry (within one year). Exclusion criteria were previous cardiovascular disease (angina pectoris, myocardial infarction, coronary intervention (percutaneous coronary intervention or coronary artery bypass grafting), heart failure, stroke, peripheral vascular disease, venous thromboembolism, atrial fibrillation or flutter, or use of digoxin, nitrates, antiplatelet drugs, or anticoagulant drugs within one year), chronic kidney disease, chronic liver disease, other alcoholism related diseases, ulcer disease, malignancy, schizophrenia (or use of antipsychotic drugs), or dementia.

Emulated trial design, to compare rates of major adverse cardiovascular events among diclofenac initiators with rates among non-initiators or initiators of active comparator drugs in Denmark. Individual level linkage of nationwide population based registries was used to emulate the eligibility criteria, washout period, treatment groups, and follow-up period of a clinical controlled trial. Eligible individuals were aged at least 18 years who had at least one year of prescription history and none of the exclusion criteria. All initiators of diclofenac and naproxen were identified during the month of January 1996. Each person was followed up to a non-fatal endpoint, death, loss to follow-up, or 30 days of follow-up. Enrolment was repeated in the months of February and March, and subsequently for every month up to December 2016. The series of 252 emulated trials were then statistically pooled into one model, generating a sample size of 1 370 832 diclofenac initiators and 291 490 naproxen initiators. A similar approach was used to identify ibuprofen initiators (n=3 878 454) and propensity score matched initiators of paracetamol (n=764 781) and NSAID non-initiators (n=1 303 209). B=baseline; MACE=major adverse cardiovascular events; D=death or emigration; F=30 days of follow-up

To increase the number of initiators and events, we subsequently applied the approach described above to every month between January 1996 and December 2016, thereby creating a series of emulated trials (n=252), each with a one month enrolment period ( fig 1 ). Fulfilling the eligible criteria at any given baseline, participants could potentially take part in several trials. Thus, NSAID non-initiators in the January 1996 “trial” could still be included in the January 1997 “trial.” By contrast, all enrolled individuals in the January 1996 “trial” were ineligible for inclusion in the subsequent 12 months.

In all models, enrolled individuals in the January trial were followed from baseline (that is, date of prescription redemption for NSAID/paracetamol initiators and general practice contact for non-initiators) until the first occurrence of a non-fatal endpoint, death, loss to follow-up, or 30 days of follow-up, whichever occurred first.

Active non-NSAID comparator: we matched paracetamol initiators from the general population to diclofenac initiators by propensity score. We used a similar matching approach as above, except for adding to the general practice contact criteria that comparators should also redeem a prescription for paracetamol within the trial month. As an analogue to the washout period in the active NSAID comparisons, we also required that paracetamol initiators and NSAID non-initiators had not been enrolled in trials in the previous 12 months.

Non-user comparators: we identified non-initiators of NSAIDs from the general population, who were alive and fulfilled the eligibility criteria in January 1996. To account for healthcare seeking behaviour, further restriction was made to individuals with a general practice contact within the trial month. We calculated the propensity score for all eligible individuals initiating diclofenac at enrolment by fitting a logistic regression model including covariates on sex, age, year, comorbidity, and drug treatment use. 15 We then matched non-initiators to diclofenac initiators (1:1) by propensity score within a maximum matching range of 0.025 and without replacement.

Active NSAID comparators: we identified initiators of ibuprofen or naproxen to enable comparison with other traditional NSAIDs. Initiation was defined as filling a first prescription within the trial month. Any person who fulfilled criteria for both the diclofenac group and an active comparator group was categorised according to the first drug redeemed. If the two drugs were redeemed on the same day, the person was excluded.

We used population based registries to emulate the eligibility criteria, washout period, treatment groups, and follow-up period of a clinical controlled trial (eTable 1). 13 14 Eligible individuals were those aged at least 18 years with at least one year of continuous prescription records before date of study entry, who did not meet the exclusion criteria (listed below), and who did not redeem NSAID prescriptions in the 12 month washout period before enrolment. Among all eligible individuals in January 1996 (the first trial month), we identified all diclofenac initiators and the following three comparator groups:

We used the Danish National Prescription Registry to identify drug use. 7 Since 1995, this registry has maintained detailed records of all prescriptions dispensed from all Danish pharmacies. 7 We obtained mortality and migration data from the Danish Civil Registration System, 8 which has recorded all changes in vital status and migration for the entire Danish population since 1968, with daily electronic updates. 8 Cause of death data were obtained from the Danish Register of Causes of Death. 12

We used the Danish National Patient Registry covering all Danish hospitals to identify the study population, their comorbidities, and non-fatal endpoints. 10 Each hospital discharge or outpatient visit (since 1977 and 1995, respectively) is recorded in the registry with one primary diagnosis and potentially several secondary diagnoses classified according to the ICD-8 (international classification of diseases, 8th revision) and ICD-10 thereafter. 10 Data on general practice contacts were obtained from the Danish National Health Insurance Service Registry. 11

Apart from low dose ibuprofen (200 mg) and diclofenac (from 16 July 2007 to 14 December 2008), all non-aspirin NSAIDs require a prescription in Denmark. 9 Regular users of over-the-counter NSAIDs have an incentive to obtain a prescription because prescription costs are partially reimbursed through the Danish national health service’s insurance programme. 9

The Danish national health service provides universal tax supported healthcare, guaranteeing unfettered access to general practitioners and hospitals, and part reimbursement for prescribed drug treatments, including diclofenac. 7 Individual level linkage of all Danish registries is possible by use of a unique personal identifier assigned to each Danish citizen at birth and to residents on immigration. 8

In sensitivity analyses, restriction to healthcare seeking behaviour among NSAID non-initiators was shown to infer important confounder control, because omission of this criterion increased the incidence rate ratio for major adverse cardiovascular events considerably (2.0, 95% confidence interval 1.8 to 2.2). Diclofenac initiation increased upper gastrointestinal bleeding risk at 30 days by approximately 2.5-fold compared with ibuprofen (incidence rate ratio 2.5, 2.1 to 3.1) or paracetamol (2.4, 2.0 to 2.9), 4.5-fold compared with no initiation (4.4, 3.5 to 5.5), and to a similar extent as naproxen (0.9, 0.7 to 1.1; eTables 11-13). The results were not influenced by potential over-the-counter use of diclofenac in part of 2007-08 (data not shown), potential crossover between exposure groups (eTable 14), restriction to only one trial entry per person (eTable 15), changes to the low dose cutoff limit (data not shown), and myocardial infarction subtype (data not shown). Finally, an unmeasured confounder that was twice as frequent among diclofenac initiators versus among non-initiators would still need to increase the risk of major adverse cardiovascular events by a factor of nine or more to fully explain the results, if no increased risk actually existed (eFigure 3).

Stratification on dose ( fig 5 and eFigure 2) revealed that the increased risk related both to low and high dose diclofenac. There was a non-significant tendency towards increased effect estimates for high doses ( fig 5 ).

Stratifying on baseline cardiovascular risk ( fig 4 and eTables 8-9), the point estimates for patients with moderate baseline cardiovascular risk were close to those in the overall analyses. For patients with high baseline risk, the incidence rate ratio remained marginally elevated compared with NSAID non-initiation (1.1, 1.0 to 1.3), but levelled out for the active comparator groups. By contrast, the additional absolute number of major adverse cardiovascular events per 1000 diclofenac initiators per year (adjusted incidence rate difference) increased with baseline risk (eTable 10). Thus, among patients at low baseline risk, diclofenac initiators had one additional event versus ibuprofen initiators, one additional event versus naproxen initiators, three additional events versus paracetamol initiators, and four additional events versus NSAID non-initiators. Among patients at moderate baseline risk, corresponding figures were seven, seven, eight, and 14 additional events, respectively; for those at high baseline risk, corresponding numbers were 16, 10, one, and 39 additional events, respectively.

The risk of major adverse cardiovascular events remained elevated in sex and age groups ( fig 3 and eTables 6-7), and across calendar periods (data not shown). While sex did not modify substantially the effect of diclofenac compared with paracetamol and ibuprofen initiation, diclofenac initiation conferred a higher risk in women than men when compared with NSAID non-initiation (incidence rate ratio 1.9 v 1.3) and naproxen initiation (1.6 v 1.2).

Diclofenac initiators had a 20% increased rate of major adverse cardiovascular events compared with ibuprofen initiators (incidence rate ratio 1.2, 95% confidence interval 1.1 to 1.3) and a 30% increased rate compared with naproxen initiators (1.3, 1.1 to 1.5; fig 2 and eTable 5). With ibuprofen as reference, the incidence rate ratio increased 1.1-fold for atrial fibrillation or flutter and heart failure, 1.2-fold for myocardial infarction, 1.3-fold for ischaemic stroke, and 1.5-fold for cardiac death. Cardiac death was driven by death due to heart failure (incidence rate ratio 1.9, 1.2 to 3.0), cardiac arrhythmias (1.7, 1.1 to 2.7), and myocardial infarction (1.4, 1.1 to 1.8). Compared with naproxen initiators, the incidence rate ratio increased 1.2-fold for ischaemic stroke, 1.3-fold for atrial fibrillation or flutter and cardiac death, 1.4-fold for myocardial infarction, and 1.5-fold for heart failure. Consistently, cardiac death was driven by death due to heart failure (incidence rate ratio 1.7, 0.6 to 5.0) and myocardial infarction (1.5, 0.8 to 2.9).

Compared with paracetamol initiators, diclofenac initiators had a 20% increased rate of major adverse cardiovascular events (incidence rate ratio 1.2, 95% confidence interval 1.1 to 1.3), reflecting a 1.2-fold increased rate of ischaemic stroke and heart failure and a 1.4-fold increased rate of atrial fibrillation or flutter and myocardial infarction ( fig 2 and eTable 5). Although overall there was no association with cardiac death (incidence rate ratio 1.0, 0.8 to 1.2), stratification on underlying causes of death revealed a substantial elevated risk of fatal myocardial infarction (1.8, 1.2 to 2.6).

Diclofenac initiators had a 50% increased rate of major adverse cardiovascular events compared with NSAID non-initiators (incidence rate ratio 1.5, 95% confidence interval 1.4 to 1.7). Supporting use of a combined endpoint, event rates consistently increased for all individual outcomes: 1.2-fold for atrial fibrillation or flutter, 1.6-fold for ischaemic stroke, 1.7-fold for heart failure, 1.9-fold for myocardial infarction, and 1.7-fold for cardiac death ( fig 2 and eTable 5). Cardiac death was driven by death from heart failure (incidence rate ratio 2.3, 1.3 to 4.2), cardiac arrhythmia (1.9, 1.1 to 3.3), and myocardial infarction (1.7, 1.2 to 2.4).

Within 30 days, major adverse cardiovascular events occurred among 1465 (0.10%) diclofenac initiators, 2912 (0.07%) ibuprofen initiators, 205 (0.07%) naproxen initiators, 967 (0.13%) paracetamol initiators, and 898 (0.07%) NSAID non-initiators (eTables 3-4). Corresponding rates of these events per 100 person years were 1.29 (95% confidence interval 1.23 to 1.36) for diclofenac initiators, 0.91 (0.88 to 0.94) for ibuprofen initiators, 0.85 (0.74 to 0.98) for naproxen initiators, 1.53 (1.44 to 1.63) for paracetamol initiators, and 0.83 (0.78 to 0.89) for NSAID non-initiators (eTables 3-4).

We identified 1 370 832 diclofenac initiators who met the inclusion criteria, 3 878 454 ibuprofen initiators, 291 490 naproxen initiators, 764 781 matched paracetamol initiators, and 1 303 209 matched non-initiators (67 623 initiators could not be matched, mainly due to advanced age; table 1 ). Men accounted for about 45% of diclofenac and ibuprofen initiators, 35% of paracetamol initiators, and 40% of naproxen initiators. The median age was 46-49 years among NSAID initiators and 56 years among paracetamol initiators. The proportion of individuals contributing to more than one trial was 31% for diclofenac (1.6% contributed to ≥5 trials), 49.6% for paracetamol (12.3%), 47% for ibuprofen (4.6%), 23% for naproxen (2.2%), and 19% for NSAID non-initiators (0.04%). Diclofenac was initiated primarily for short term treatment. Thus, 44% of patients redeemed one prescription, 19% redeemed two, and 10% redeemed three; only 9% redeemed 10 or more prescriptions. Most diclofenac initiators (75%) redeemed only one prescription within six months of initiation. The design yielded fairly equal distributions of comorbidities and drug treatment use across exposure groups (standardised differences <10%), indicating that diclofenac and ibuprofen/naproxen initiators had similar characteristics and that the propensity score matching was successful ( table 1 and eFigure 1).

Discussion

In our study, we found that diclofenac initiators were at increased risk of major adverse cardiovascular events—both compared with no NSAID initiation, initiation of paracetamol as an analgesic alternative to NSAIDs, as well as initiation of other traditional NSAIDs. Risk estimates compared with no initiation, paracetamol initiation, and ibuprofen or naproxen initiation increased for almost all individual components of major adverse cardiovascular events (that is, atrial fibrillation or flutter, ischaemic stroke, heart failure, acute myocardial infarction, and cardiac death). The risk increase applied to men and women of all ages. Although the absolute risks were highest in individuals with high baseline cardiovascular risk, the relative risks were highest in those with the lowest baseline risk. While NSAID use previously was considered risk-neutral in short treatment periods and low doses,20 the risks were apparent even within 30 days and also for low doses of diclofenac. Finally, the upper gastrointestinal bleeding risk of diclofenac was comparable to that for naproxen, but considerably higher than for paracetamol use, ibuprofen use, and no use.

Strengths and limitations The Danish registry infrastructure made the emulated trial design possible. To our knowledge, the sample size of more than 6.3 million initiators of diclofenac, paracetamol, ibuprofen, or naproxen is larger than all previous meta-analyses of observational and randomised studies taken together.3212223 The largest meta-analysis of randomised trials (Coxib and traditional NSAID Trialists’ Collaboration) included only 70 major vascular events in 158 trials comparing traditional NSAIDs with placebo (38 081 participants; 16 217 person years) and 24 major vascular events in 335 trials comparing different traditional NSAIDs (68 507; 22 418).3 By comparison, our study included over 4500 adverse events among NSAID initiators, close to 1000 adverse events among paracetamol initiators, and a similar number among non-initiators. The tendency we observed for reduced relative risk estimates as baseline risk increased and in comparisons with active comparator drugs is consistent with the principle that effect estimates are highest among individuals at lowest baseline risk. The population based design in the setting of a tax supported, universal healthcare system largely removed selection biases stemming from selective inclusion of specific hospitals, health insurance systems, or age groups. The study had no missing data on exposure, confounders, or events. The prescription registry permitted identification of diclofenac use and is virtually complete.79 Our new user design resembled drug allocation in randomised controlled trials.24 Although we had to use prescription data as a proxy for actual NSAID use, we did not base drug exposure information on written prescriptions, but on actual dispensing at pharmacies.7 Required copayments increased the likelihood of compliance,25 although non-compliance in taking the prescribed tablet dose could have masked a dose-response effect. Over-the-counter use of low dose ibuprofen accounted for 30-35% of total ibuprofen sales and 15-25% of total NSAID sales during the study period.7 As shown, misclassification of diclofenac use did not affect the results substantially. Non-differential misclassification by over-the-counter ibuprofen use would bias the effect estimates towards unity, if it occurred, and cannot explain the results. The cardiovascular registry diagnoses used in the study have been validated26 and the mortality and migration data were accurate and complete.8 Although the models of healthcare seeking non-initiators and paracetamol initiators varied by design compared with the active NSAID comparators (propensity score matching v adjustment), both were based on and controlled for the same measured covariates. The fairly equal distribution of measured covariates among the NSAID groups increased the likelihood that unmeasured variables were also equally distributed. Moreover, confounding by indication was not a concern in the active drug comparisons owing to the shared indications for use of traditional NSAIDs. Still, the emulated trial design lacked baseline randomisation, and therefore, unmeasured confounding cannot be excluded.

Mechanisms Owing to its short half life of 1-2 hours, diclofenac is prescribed at doses high enough for effective analgesia throughout the dosing interval. The plasma concentration of diclofenac therefore greatly exceeds that necessary to inhibit COX-2 early in the dosing interval, and coincidently inhibits COX-1 (attained selectivity).27 As plasma concentration falls, diclofenac continues to inhibit COX-2 completely, while its effect on COX-1 subsides gradually, generating a window of pure COX-2 inhibition.28 Neither ibuprofen nor naproxen show such a window, because their inhibition of COX-1 exceeds that of COX-2 throughout the dosing interval.27 Selective COX-2 inhibition favours thrombosis by inhibiting generation of COX-2 derived vascular prostacyclin while not affecting COX-1 mediated thromboxane A 2 .29 Other factors contributing to the cardiovascular toxicity of COX-2 inhibitors include acceleration of atherogenesis,30 elevation or destabilisation of blood pressure,31 and risk of heart failure decompensation.3233 COX-2 derived prostacyclin also acts as an endogenous anti-arrhythmic agent through inhibition of epicardial sympathetic nerve activity.343536 COX-2 inhibition could therefore render patients more susceptible to arrhythmias such as atrial fibrillation.27 The inhibition of COX-2 up regulation might be particularly harmful during myocardial ischaemia, because thromboxane and prostacyclin are released from the acutely ischaemic myocardium and their balance is related to arrhythmia risk37 and infarct size.38

Previous literature This large study directly compares the risks of diclofenac initiation with those of paracetamol, ibuprofen, and naproxen for various cardiovascular outcomes. Comparing diclofenac initiation with no NSAID initiation, the consistency between our results and those of previous meta-analyses of both trial and observational data provides strong evidence to guide clinical decision making. The Coxib and traditional NSAID Trialists’ Collaboration meta-analysis found a 40% increased risk of vascular events associated with diclofenac use versus placebo or no use (incidence rate ratio 1.41, 95% confidence interval 1.12 to 1.78), driven by an increased rate of myocardial infarction (1.70, 1.19 to 2.41).3 Also in line with our results, the meta-analysis showed that diclofenac users had an increased risk of heart failure (1.85, 1.17 to 2.94) and vascular death (1.65, 0.95 to 2.85).3 The discrepancy between our estimated 60% increased risk and the meta-analysis’ estimate for any stroke (1.18, 0.79 to 1.78) could be explained by our focus on ischaemic stroke.3 The incidence rate ratio for atrial fibrillation or flutter found in our study was lower than previously reported (1.73, 1.53-1.97),39 in part owing to our ability to control for healthcare seeking behaviour. Finally, the meta-analysis estimated the excess absolute rate of major adverse cardiovascular events per 1000 diclofenac initiators per year as three events among low risk individuals (of which one was fatal) and seven to eight events among high risk individuals (of which two were fatal).3 Compared with non-initiators, we found a similar excess rate among low risk individuals (about four major adverse cardiovascular events, including one fatal cardiac event), but an even greater rate in high risk individuals (about 40 events, of which about half were fatal).