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Differing association of alcohol consumption with different stroke types: a systematic review and meta-analysis
Received: 12 July 2016
Accepted: 17 October 2016
Published: 24 November 2016
Abstract
Background
Whether light-to-moderate alcohol consumption is protective against stroke, and whether any association differs by stroke type, is controversial. We conducted a meta-analysis to summarize the evidence from prospective studies on alcohol drinking and stroke types.
Methods
Studies were identified by searching PubMed to September 1, 2016, and reference lists of retrieved articles. Additional data from 73,587 Swedish adults in two prospective studies were included. Study-specific results were combined in a random-effects model.
Results
The meta-analysis included 27 prospective studies with data on ischemic stroke (25 studies), intracerebral hemorrhage (11 studies), and/or subarachnoid hemorrhage (11 studies). Light and moderate alcohol consumption was associated with a lower risk of ischemic stroke, whereas high and heavy drinking was associated with an increased risk; the overall RRs were 0.90 (95 % CI, 0.85–0.95) for less than 1 drink/day, 0.92 (95 % CI, 0.87–0.97) for 1–2 drinks/day, 1.08 (95 % CI, 1.01–1.15) for more than 2–4 drinks/day, and 1.14 (95 % CI, 1.02–1.28) for more than 4 drinks/day. Light and moderate alcohol drinking was not associated with any hemorrhagic stroke subtype. High alcohol consumption (>2–4 drinks/day) was associated with a non-significant increased risk of both hemorrhagic stroke subtypes, and the relative risk for heavy drinking (>4 drinks/day) were 1.67 (95 % CI, 1.25–2.23) for intracerebral hemorrhage and 1.82 (95 % CI, 1.18–2.82) for subarachnoid hemorrhage.
Conclusion
Light and moderate alcohol consumption was inversely associated only with ischemic stroke, whereas heavy drinking was associated with increased risk of all stroke types with a stronger association for hemorrhagic strokes.
Keywords
Background
Whether light-to-moderate alcohol consumption, generally defined as 1–2 drinks per day, is protective against cardiovascular disease remains a controversial topic. Alcohol consumption in moderation has been associated with increased high-density lipoprotein cholesterol, improved insulin sensitivity, and decreased levels of fibrinogen and inflammatory markers [1–4]. Moreover, alcohol intake is associated with risk of hypertension in a linear positive dose–response relationship in men and with a J-shaped dose–response relationship in women [5]. Whereas observational studies have consistently reported an inverse association between moderate alcohol consumption and risk of ischemic heart disease [6, 7], the association between alcohol consumption and risk of stroke types has not been delineated. Previous meta-analyses of alcohol consumption and stroke risk examined only total stroke (ischemic and all hemorrhagic strokes combined) [6] or combined case-control and prospective studies in the analysis of stroke types [8, 9]. Whether the association of alcohol consumption with risk of hemorrhagic stroke varies for intracerebral hemorrhage and subarachnoid hemorrhage was not addressed in previous meta-analyses.
The aim of this study was to perform a contemporary systematic review and meta-analysis to summarize available evidence from prospective studies on alcohol consumption in relation to risk of ischemic stroke, intracerebral hemorrhage, and subarachnoid hemorrhage. Moreover, we investigated the association between alcohol consumption and incidence of stroke types in 4555 stroke cases with a mean of 11.9 years of follow-up in the Cohort of Swedish Men (COSM) and the Swedish Mammography Cohort (SMC), and included these cohorts in the present meta-analysis.
Methods
Swedish cohort studies
Details about the COSM and the SMC, assessment of alcohol consumption and covariates, case ascertainment, and statistical analysis are reported in Additional file 1: Text S1. The study population for this analysis consisted of 39,941 men (45–79 years of age) in the COSM and 33,646 women (49–83 years of age) in the SMC. Participants were free of stroke and ischemic heart disease at baseline (January 1, 1998) and were followed up through December 31, 2010.
Meta-analysis
Search strategy
The design, analysis, and reporting for this meta-analysis followed the MOOSE guidelines [10]. Relevant studies were identified by a literature search of the PubMed database (from January 1966 to September 1, 2016), without restrictions, using the search terms “alcohol consumption”, “alcohol drinking”, or “alcohol intake” combined with “stroke”, or “cerebrovascular disease”, or “cerebral infarction”, or “intracerebral hemorrhage” or “subarachnoid hemorrhage”. The database search was performed by two authors (SCL and AWa) and enhanced by searches of the reference lists of identified articles.
Inclusion criteria
Two authors (SCL and AWa) independently evaluated all records by title, abstract, or full text for potentially eligible studies, and any disagreement was resolved by consensus. Eligible for inclusion in the meta-analysis were prospective studies that reported relative risks (RR) with 95 % confidence intervals (CI) for quantitative categories of alcohol consumption in relation to non-fatal or fatal ischemic stroke, intracerebral hemorrhage, or subarachnoid hemorrhage. Studies that only reported data on total stroke (ischemic and hemorrhagic strokes combined) or total hemorrhagic stroke were not eligible. Where duplicate publications were available from the same study population, the study with data on stroke types and the largest number of stroke cases was included.
Data extraction and quality assessment
Details recorded for each study were the first author’s surname, publication year, study name, country in which the study was performed, number of subjects, proportion of men, age range, mean follow-up, number of cases for each stroke type, method used for assessment of alcohol consumption, average or range of alcohol intake as well as number of cases and person-years (or non-cases if person-years were not provided) in each category, RRs with 95 % confidence intervals (CIs) for each category, and covariates controlled for in the most fully adjusted multivariable model. Study quality was evaluated with the Newcastle–Ottawa Scale [11]. The quality score ranged from 0 to 9. Details of how the criteria were applied are described in Additional file 1: Figure S1.
Statistical analysis
To place the studies on a common scale, alcohol consumption was standardized to drinks of alcohol. If alcohol consumption was reported in grams, the values were converted into drinks by assuming that one drink on average contains 12 grams of alcohol. The median or mean alcohol intake for each category was assigned to the corresponding risk estimate. If average values were not reported, each category was assigned the midpoint of the upper and lower boundaries for that category. If an upper boundary was not provided for the highest category, the boundary was presumed to have the same range as the adjacent category. In a sensitivity analysis, for studies that did not provide the average value for the highest category, the mid-point for the highest category was set at 1.5 times the half range of the preceding category.
A random-effects model was used to combine study-specific RRs by alcohol consumption categories based on the average consumption in each category. The exposure categories were as follows: light (< 1 drink/day), moderate (1–2 drinks/day), high (> 2–4 drinks/day), and heavy (> 4 drinks/day) alcohol consumption. The comparison group was the reference group in each study (i.e., non-drinkers, never drinkers, or occasional drinkers). In a sensitivity analysis, we stratified the studies by reference group used.
Meta-regression and subgroup analyses were performed to assess whether the association between alcohol consumption and stroke types varied by geographic region (United States, Europe, and Asia), sex, and study quality (Newcastle–Ottawa Scale: < 7 vs. ≥ 7). Because of the small number of studies in some subgroups, the light and moderate alcohol consumption categories and the high and heavy alcohol consumption categories were combined. In a sensitivity analysis for women, we defined 1 or less drinks/day as the moderate alcohol consumption category and more than 1 drink/day as high-to-heavy alcohol drinking. Between-study heterogeneity was evaluated with the I 2 statistic [12], and the degree of heterogeneity was quantified using the following cutoff values: less than 30 %, no or low heterogeneity; 30–75 %, moderate heterogeneity; and more than 75 %, notable heterogeneity. Egger’s test was used to assess small-study bias such as publication bias [13]. Statistical tests were considered statistically significant at P values < 0.05. All analyses were conducted using Stata (version 14.1, StataCorp, College Station, TX).
Results
Swedish cohort studies
Baseline characteristics of men in the COSM and women in the SMC are shown in Additional file 1: Table S1. A total of 3824 ischemic stroke cases (2216 in men and 1608 in women), 555 intracerebral hemorrhage cases (350 in men and 205 in women), and 176 subarachnoid hemorrhage cases (82 in men and 94 in women) were ascertained over 873,440 person-years (mean 11.9 years) of follow-up. There was no statistically significant association between alcohol consumption and risk of ischemic stroke (Additional file 1: Table S2). However, because of the small number of cases in some categories, we cannot exclude weak associations. Consumption of more than 21 drinks/week of alcohol was associated with a statistically significant increased risk of intracerebral hemorrhage in both men and women (Additional file 1: Table S2). Alcohol consumption was statistically significantly positively associated with subarachnoid hemorrhage in women but not in men (Additional file 1: Table S2).
Meta-analysis
Prospective studies of alcohol consumption and risk of ischemic stroke, intracerebral hemorrhage, and subarachnoid hemorrhage
No. of stroke cases | ||||||||||
|---|---|---|---|---|---|---|---|---|---|---|
Study | Cohort name, country | No. of subjects | Age, years | Men, % | Follow-up, years | IS | ICH | SAH | NOS score | Adjustments |
Donahue et al., 1986 [14] | Honolulu Heart Program, USA | 8006 | 45–69 | 100 | 12 | 190 | 44 | 32 | 8 | Age, smoking, BMI, hypertensive status, serum cholesterol, uric acid glucose, and hematocrit concentrations |
Stampfer et al., 1988 [15] | Nurses’ Health Study, USA | 87,526 | 34–59 | 0 | 3.8 | –a | – | 28 | 7 | Age, smoking, obesity, exercise, family history of myocardial infarction, menopausal status and hormone use, history of hypertension, high cholesterol levels, diabetes, intake of cholesterol, saturated fat, and polyunsaturated fat |
Iso et al., 1995 [16] | Rural Japanese Cohorts, Japan | 2890 | 40–69 | 100 | 10.5 | 104 | – | – | 8 | Age, smoking, hypertension, serum total cholesterol, and diabetes |
Kiyohara et al., 1995 [17] | The Hisayama Study, Japan | 1621 | ≥ 40 | 44 | 26 | 244 | 60 | – | 9 | Age, sex, BMI, hypertension, electrocardiographic abnormalities, heart rate, glucose intolerance, serum cholesterol, and smoking |
Leppälä et al., 1999 [18] | Alpha-Tocopherol, Beta-Carotene Cancer Prevention Study, Finland | 26,556 | 50–69 | 100 | 6.1 | 733 | 95 | 83 | 7 | Age, randomized treatment assignment, education, smoking, BMI, physical activity, serum total cholesterol, history of heart disease, diabetes |
Sankai et al., 2000 [19] | Six Japanese Communities, Japan | 12,372 | 40–69 | 40 | 9.4 | – | – | 71 | 8 | Age, sex, smoking, BMI, blood pressure, serum total cholesterol, diabetes |
Suh et al., 2001 [20] | Korea Medical Insurance Corporation Study, Korea | 114,793 | 35–59 | 100 | 5.4 | – | 373 | 98 | 6 | Age, smoking, BMI, blood pressure, fasting blood glucose, total serum cholesterol |
Klatsky et al., 2001 [21] | Kaiser Permanente Medical Care Program Cohort, USA | 128,934 | < 40–70+ | 44 | 18 | 2014 | – | – | 6 | Age, sex, race, education, smoking, BMI |
Klatsky et al., 2002 [22] | Kaiser Permanente Medical Care Program Cohort, USA | 128,934 | < 40–70+ | 44 | 18 | – | 299 | 133 | 6 | Age, sex, race, education, smoking, BMI |
Djousse et al., 2002 [23] | Framingham Study, USA | 9171 | ≥ 50 | 42 | 8.8 | 441 | – | – | 7 | Age, smoking, BMI, diabetes |
Iso et al., 2004 [24] | Japan Public Health Centre-Based Prospective Study, Japan | 19,356 | 40–59 | 100 | 11.0 | 319 | 219 | 73 | 6 | Age, education, public health centers, smoking, BMI, sports at leisure time, history of diabetes, intakes of fruit, vegetable, and fish |
Iwashita et al., 2005 [25] | Kyushu Lipid Intervention Study, Japan | 4349 | 45–74 | 100 | 5 | 81 | – | – | 6 | Age, smoking, BMI, serum total cholesterol, high-density lipoprotein cholesterol, prior use of cholesterol-lowering drugs, history of angina, hypertension, and diabetes |
Mukamal et al, 2005 [26] | Cardiovascular Health Study, USA | 4410 | ≥ 65 | 36 | 9.2 | 434 | – | – | 7 | Age, sex, geographic region, parental history of myocardial infarction, smoking, BMI, physical activity, hypercholesterolemia, diabetes, aspirin use, intakes of energy, vitamin E, folate, saturated fat, trans fats, omega-3 fatty acids, potassium, magnesium, and dietary fiber |
Nielsen et al., 2005 [27] | Copenhagen City Heart Study, Denmark | 12,096 | 21–98 | 44 | 15 | 786 | – | – | 8 | Age, sex, education, smoking, BMI, physical activity, systolic blood pressure, history of myocardial infarction and diabetes, Forced Expiratory Volume 1 |
Elkind et al., 2006 [28] | Northern Manhattan Study, USA | 3176 | ≥ 40 | 37 | 5.9 | 172 | – | – | 8 | Age, sex, race/ethnicity, education, smoking, high-density lipoprotein cholesterol, history of hypertension, atrial fibrillation, and diabetes |
Bazzano et al., 2007 [29] | China National Hypertension Survey Epidemiology Follow-up Study, China | 64,338 | ≥ 40 | 100 | 7.7 | 1724 | – | – | 8 | Age, geographic region, urban or rural residence, education, smoking, BMI, physical activity, diabetes |
Sturgeon et al, 2007 [30] | Atherosclerosis Risk in Communities Study and Cardiovascular Health Study, USA | 21,680 | ≥ 45 | 45 and 42 | 12.2 | – | 135 | – | 5 | Age |
Chiuve et al., 2008 [31]b | Health Professionals Follow-up Study, USA | 43,685 | 40–75 | 100 | 18 | 600 | – | – | 6 | Age, calendar year, family history of myocardial infarction, aspirin use, vitamin E supplementation |
Lu et al., 2008 [32] | Swedish Women’s Lifestyle and Health Cohort Study, Sweden | 45,449 | 30–50 | 0 | 11 | 111 | 47 | – | 7 | Age, education, BMI, smoking, parity and age at first birth, oral contraceptive use |
Sandvei et al., 2009 [33] | Nord-Trøndelag Health Study, Norway | 61,371 | ≥ 20 | 49 | 22 | – | – | 132 | 4 | Age, sex |
Bos et al., 2010 [34] | European Investigation into Cancer and Nutrition-Netherlands Cohort, The Netherlands | 10,530 | 20–70 | 0 | 9.4 | 165 | – | – | 8 | Age, cohort, education, smoking, BMI, physical activity, menopausal status, hypercholesterolemia, diabetes, antihypertensive medication, intakes of energy, vitamin E, vitamin C, saturated fat, and fiber |
Rist et al., 2010 [35] | Physicians’ Health Study, USA | 21,860 | 40–84 | 100 | 21.6 | 1157 | – | – | 8 | Age, smoking, BMI, exercise, systolic blood pressure, treatment for hypertension, diabetes, and migraine |
Zhang et al., 2011 [36] | Six geographic areas of Finland | 36,686 | 25–74 | 47 | 13.7 | 1167 | – | – | 8 | Age, study year, sex, education, smoking, BMI, physical activity, systolic blood pressure, total cholesterol level, family history of stroke, diabetes, intake of fruit and vegetables |
Higashiyama et al., 2011 [37] | Suita Study, Japan | 2336 | 30–79 | 100 | 12.5 | 78 | – | – | 7 | Age, smoking, BMI, high-density lipoprotein cholesterol, triglycerides, history of hypercholesterolemia, hypertension, and diabetes |
Drogan et al., 2012 [38] | European Investigation into Cancer and Nutrition-Potsdam cohort, Germany | 2175 | 35–65 | 37 | 8.2 | 169 | – | – | 7 | Age, education, smoking, BMI, waist circumference, physical activity, hypertension, diabetes, plasma total cholesterol levels, and non-alcohol energy intake |
Jimenez et al., 2012 [39] | Nurses’ Health Study, USA | 83,578 | 30–55 | 0 | 20.3 | 1206 | – | – | 8 | Age, education, marital status, family history of heart disease, smoking, BMI, physical activity, postmenopausal status, hormone therapy use, aspirin use, high cholesterol, history of heart disease and diabetes, bilateral oophorectomy, multivitamin use, diet score |
Ikehara et al., 2013 [40] | Japan Public Health Centre-Based Prospective Study, Japan | 47,100 | 40–69 | 0 | 16.7 | 964 | 532 | 338 | 8 | Age, area, smoking, BMI, sports at leisure-time, history of hypertension and diabetes, flushing after alcohol drinking, mental stress, menopausal status |
Kadlecová et al., 2015 [41] | Swedish Twin Registry, Sweden | 11,644 | ≤ 60 | 30 | 29.1 | 1846 | – | – | 8 | Age, sex, smoking, BMI, exercise, history of coronary heart disease, hypertension, diabetes and depression, stress reactivity |
Jones et al., 2015 [42] | Atherosclerosis Risk in Communities study, USA | 12,433 | 45–64 | 45 | 22.6 | 773 | –c | – | 6 | Age, sex, center-race interaction, education, smoking; IS analyses were further adjusted for low-density lipoprotein cholesterol, history of coronary heart disease and diabetes, marital status, diet score |
Larsson et al., 2016 (current study) | Cohort of Swedish Men, Sweden | 39,941 | 45–79 | 100 | 11.9 | 2216 | 350 | 82 | 8 | Age, education, family history of myocardial infarction, smoking, BMI, exercise, walking/bicycling, history of hypertension, hypercholesterolemia, atrial fibrillation, and diabetes, aspirin use, diet score |
Larsson et al., 2016 (current study) | Swedish Mammography Cohort, Sweden | 33,646 | 49–83 | 0 | 11.9 | 1608 | 205 | 94 | 8 | Age, education, family history of myocardial infarction, smoking, BMI, exercise, walking/bicycling, history of hypertension, hypercholesterolemia, atrial fibrillation, and diabetes, aspirin use, diet score |
Overall analyses
Overall relative risks (RR) with 95 % confidence intervals (CI) for the associations of alcohol consumption (average number of drinks per day) with risk of ischemic stroke, intracerebral hemorrhage, and subarachnoid hemorrhage. *Number of studies that contributed data to each category of alcohol consumption and stroke type. I 2 values < 30 %, 30–75 %, and > 75 % were interpreted as no or low heterogeneity, moderate heterogeneity, and notable heterogeneity, respectively
Subgroup analyses
Relative risks of stroke types for light-to-moderate and high-to-heavy alcohol consumption, overall and stratified by geographic area, sex, and study quality
Alcohol consumption | ||||||
|---|---|---|---|---|---|---|
Light-to-moderate (≤ 2 drinks/day) | High-to-heavy (> 2 drinks/day) | |||||
No.a | RR (95 % CI) | I 2b | No.a | RR (95 % CI) | I 2b | |
Ischemic stroke | ||||||
All studies | 24 | 0.91 (0.88–0.94) | 9.1 % | 23 | 1.09 (1.03–1.16) | 0 % |
Geographic area | ||||||
United States | 9 | 0.90 (0.85–0.94) | 7.7 % | 8 | 1.12 (1.01–1.24) | 0 % |
Europe | 9 | 0.93 (0.88–0.98) | 11.1 % | 8 | 1.14 (1.04–1.25) | 0 % |
Asia | 5 | 0.87 (0.78–0.98) | 10.6 % | 6 | 1.07 (0.93–1.23) | 30.6 % |
Sex | ||||||
Men | 12 | 0.94 (0.88–1.00) | 18.4 % | 10 | 1.11 (1.00–1.23) | 15.2 % |
Women | 7 | 0.88 (0.83–0.95) | 0 % | 6 | 1.15 (0.96–1.36) | 0 % |
Womenc | 7 | 0.88 (0.79–0.98) | 32.2 % | 7 | 0.96 (0.85–1.08) | 7.9 % |
Study quality | ||||||
NOS ≥ 7 | 18 | 0.90 (0.86–0.93) | 0 % | 17 | 1.09 (1.02–1.16) | 0 % |
NOS < 7 | 5 | 0.87 (0.81–0.94) | 13.6 % | 4 | 1.10 (0.97–1.25) | 9.3 % |
Intracerebral hemorrhage | ||||||
All studies | 11 | 0.95 (0.84–1.07) | 10.2 % | 9 | 1.45 (1.18–1.78) | 55.0 % |
Geographic area | ||||||
United States | 3 | 0.94 (0.75–1.17) | 33.4 % | 2 | 1.38 (0.86–2.21) | 33.6 % |
Europe | 4 | 0.92 (0.77–1.10) | 0 % | 3 | 1.39 (0.98–1.96) | 40.2 % |
Asia | 4 | 1.09 (0.79–1.49) | 34.1 % | 4 | 1.56 (1.13–2.17) | 69.7 % |
Sex | ||||||
Men | 5 | 0.98 (0.78–1.24) | 26.4 % | 5 | 1.35 (1.06–1.72) | 59.4 % |
Women | 3 | 0.95 (0.76–1.19) | 0 % | 2 | 2.23 (1.47–3.38) | 0 % |
Womenc | 3 | 0.81 (0.55–1.19) | 37.6 % | 3 | 1.54 (1.08–2.18) | 29.6 % |
Study quality | ||||||
NOS ≥ 7 | 7 | 0.99 (0.84–1.18) | 7.5 % | 6 | 1.68 (1.32–2.14) | 25.4 % |
NOS < 7 | 4 | 0.90 (0.76–1.07) | 17.0 % | 3 | 1.20 (0.92–1.56) | 51.9 % |
Subarachnoid hemorrhage | ||||||
All studies | 10 | 1.16 (0.98–1.37) | 0 % | 9 | 1.57 (1.18–2.09) | 39.0 % |
Geographic area | ||||||
United States | 3 | 1.46 (1.02–2.10) | 21.4 % | 2 | 2.04 (1.12–3.73) | 24.4 % |
Europe | 4 | 1.03 (0.81–1.30) | 0 % | 3 | 1.17 (0.58–2.37) | 58.9 % |
Asia | 3 | 1.26 (0.81–1.97) | 19.8 % | 4 | 1.57 (1.10–2.24) | 31.3 % |
Sex | ||||||
Men | 5 | 1.06 (0.69–1.60) | 29.9 % | 5 | 1.48 (0.96–2.28) | 51.0 % |
Women | 3 | 1.38 (1.04–1.85) | 0 % | 2 | 1.90 (1.16–3.13) | 0 % |
Womenc | 3 | 1.56 (1.01–2.38) | 19.5 % | 3 | 1.54 (1.08–2.20) | 0 % |
Study quality | ||||||
NOS ≥ 7 | 7 | 1.25 (0.97–1.62) | 13.4 % | 3 | 1.44 (1.01–2.06) | 16.5 % |
NOS < 7 | 4 | 1.10 (0.87–1.39) | 0 % | 6 | 1.57 (1.03–2.40) | 50.0 % |
The association between alcohol consumption and stroke types did not differ appreciably by reference group used, except that light-to-moderate drinking was not associated with ischemic stroke when occasional drinkers were used as the comparison group (Additional file 1: Table S3).
Small-study bias
Indication of small-study bias was observed in the light alcohol consumption category for ischemic stroke (P = 0.04) and subarachnoid hemorrhage (P = 0.01), but not in the moderate, high, and heavy alcohol consumption categories. There was no evidence of small-study bias for subarachnoid hemorrhage.
Discussion
Findings from this meta-analysis of 27 prospective studies indicate that alcohol consumption has divergent associations by stroke type. Light and moderate alcohol consumption (up to 2 drinks/day) was associated with a reduced risk of ischemic stroke but was not associated with risk of intracerebral or subarachnoid hemorrhage. Heavy alcohol consumption was associated with an increased risk of all stroke types but with stronger associations for hemorrhagic stroke subtypes than for ischemic stroke.
The divergent dose–response relationships between alcohol consumption and risk of ischemic stroke and hemorrhagic stroke subtypes suggest that different mechanisms underlie associations with the different stroke types. Alcohol consumption is associated with increased high-density lipoprotein cholesterol levels and reduced fibrinogen levels [1–4], and this might explain the lower the risk of ischemic stroke but not hemorrhagic stroke associated with light and moderate alcohol consumption. The adverse impact of alcohol consumption on blood pressure may directly increase the risk of hemorrhagic stroke and outweigh potential beneficial associations of light to moderate drinking with ischemic stroke.
Ischemic stroke itself is caused by a number of different pathophysiological mechanisms and alcohol drinking might have contrasting effects on different ischemic stroke subtypes. For example, moderate and high alcohol consumption is associated with an elevated risk of atrial fibrillation [43], which is a risk factor for cardioembolic stroke. However, only one study in this meta-analysis reported results for ischemic stroke subtypes [24]. Results from that cohort study of Japanese men showed that moderate and heavy alcohol consumption was associated with a non-statistically significant increased risk of cardioembolic stroke, whereas moderate alcohol consumption was associated with a statistically significant reduced risk of lacunar infarction and a non-statistically significant lower risk of large artery stroke [24].
Although the overall evidence from prospective observational studies indicates an inverse association between light-to-moderate alcohol consumption and risk of ischemic stroke, the causality of this association is unclear. Further information on causality can be obtained by looking at genetic associations. This approach, known as Mendelian randomization, avoids some of the crucial limitations of observational studies because allocation of genetic variants is random with regard to potential confounders. A recent Mendelian randomization study shed doubts on the beneficial effects of moderate alcohol consumption on cardiovascular disease. That study showed that individuals with an alcohol dehydrogenase 1B gene variant, which is associated with nondrinking and lower levels of usual alcohol consumption, had a reduced risk of ischemic stroke [44]. However, the gene studied explains only a fraction of alcohol consumption in the population and it may have effects on cardiovascular disease beyond those explained by alcohol consumption. Therefore, it has been suggested that the alcohol dehydrogenase 1B gene allele violates the assumptions required for a variable for Mendelian randomization and is therefore inappropriate for judging the effects of alcohol consumption on cardiovascular disease [45]. To further evaluate the causality of the inverse association between light-to-moderate alcohol consumption and ischemic stroke, additional Mendelian randomization studies that use a better instrumental variable than a single nucleotide polymorphism of the alcohol dehydrogenase 1B gene are required.
A strength of the present meta-analysis is the relatively large number of studies included. Therefore, the association between alcohol consumption and stroke types could be estimated with a relatively high accuracy across a wide range of alcohol consumption, and in different subgroups. In addition, by inclusion of prospective studies, only the possibility that the results may have been affected by recall or selection bias, which could be of concern in case–control studies, was minimized.
This meta-analysis is limited by the lack of individual patient data. We therefore could not adjust the risk estimates for the same covariates in all studies. Some degree of underreporting of alcohol consumption by participants in the included studies is likely to have occurred. Such underreporting would underestimate the threshold for adverse effects of alcohol consumption on stroke risk. Another limitation is that the major type of alcoholic beverage consumed and the drinking pattern differ across populations and this could introduce between-study heterogeneity. Nevertheless, we conducted stratified analyses by geographic area, which in part could account for different alcohol consumption patterns, and found similar associations across regions. Alcohol consumption patterns may be different for populations in southern compared with northern Europe. Because all European studies of alcohol consumption and stroke types were conducted in northern Europe (mainly in the Nordic countries), we could not investigate potential differences in alcohol–stroke type associations for northern versus southern European populations. A further shortcoming is that the association of alcohol consumption with etiologic subtypes of ischemic stroke could not be assessed. Finally, as in any meta-analysis, small-study bias (e.g., publication bias) could be of concern. There was evidence of such bias in the light alcohol consumption category for both ischemic stroke and subarachnoid hemorrhage. Hence, we cannot rule out the possibility that the associations between light alcohol drinking and risk of ischemic stroke and subarachnoid hemorrhage have been overestimated. No indication of small-study bias was observed in the analyses of intracerebral hemorrhage.
Future studies should evaluate the association of alcohol drinking patterns (regular or binge drinking) and usual type of beverage (wine, beer, and liquor) consumed with risk of stroke and ischemic stroke subtypes (large vessel, small vessel, and cardioembolic stroke). Furthermore, future studies should assess underreporting of alcohol intake and may use new approaches for estimating alcohol consumption based on metabolic profiling [46], which offers promise as a way of avoiding errors in self-reporting of alcohol consumption.
Conclusions
Findings from this meta-analysis indicate that alcohol consumption has divergent effects on different stroke types. This may explain some of the inconsistent results from previous studies associating alcohol consummation with all strokes.
Abbreviations
- CI:
-
confidence interval
- COSM:
-
Cohort of Swedish Men
- RR:
-
relative risk
- SMC:
-
Swedish Mammography Cohort
Declarations
Acknowledgements
This work was funded by the Swedish Stroke Association. AWo has received funding from the Swedish Research Council/Committee for Research Infrastructures for maintenance of the Swedish cohorts. SCL is supported by a Junior Researcher Award from the Strategic Research Area in Epidemiology at Karolinska Institutet. HSM is supported by a National Institute for Health Research (NIHR) Senior Investigator award, and his work is supported by the Cambridge Universities NIHR Comprehensive Biomedical Research Centre. The funders had no role in the design, collection, analysis, or interpretation of data, in the writing of the manuscript, or in the decision to submit the manuscript for publication.
Availability of data and materials
These data are not publicly available as these concern patient-related data.
Authors’ contributions
SCL had full access to all of the data in the study and take responsibility for the integrity of the data and the accuracy of the data analysis. Study concept and design: SCL, AWa, AWo, and HSM. Acquisition of data: SCL, AWa, AWo. Statistical analysis: SCL. Interpretation of data: SCL, AWa, AWo, and HSM. Drafting the manuscript: SCL. Critical revision of manuscript for important intellectual content: SCL, AWa, AWo, and HSM. Obtained funding: SCL, AWo, and HSM. Study supervision: HSM. All authors have read and approved the final manuscript.
Competing interests
The authors declare that they have no competing interests.
Open AccessThis article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.
Authors’ Affiliations
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