Roberto Pastor-Barriuso

Arsenic exposure and prevalence of type 2 diabetes in US adults.

CONTEXT High chronic exposure to inorganic arsenic in drinking water has been related to diabetes development, but the effect of exposure to low to moderate levels of inorganic arsenic on diabetes risk is unknown. In contrast, arsenobetaine, an organic arsenic compound derived from seafood intake, is considered nontoxic. OBJECTIVE To investigate the association of arsenic exposure, as measured in urine, with the prevalence of type 2 diabetes in a representative sample of US adults. DESIGN, SETTING, AND PARTICIPANTS Cross-sectional study in 788 adults aged 20 years or older who participated in the 2003-2004 National Health and Nutrition Examination Survey (NHANES) and had urine arsenic determinations. MAIN OUTCOME MEASURE Prevalence of type 2 diabetes across intake of arsenic. RESULTS The median urine levels of total arsenic, dimethylarsinate, and arsenobetaine were 7.1, 3.0, and 0.9 mug/L, respectively. The prevalence of type 2 diabetes was 7.7%. After adjustment for diabetes risk factors and markers of seafood intake, participants with type 2 diabetes had a 26% higher level of total arsenic (95% confidence interval [CI], 2.0%-56.0%) and a nonsignificant 10% higher level of dimethylarsinate (95% CI, -8.0% to 33.0%) than participants without type 2 diabetes, and levels of arsenobetaine were similar to those of participants without type 2 diabetes. After similar adjustment, the odds ratios for type 2 diabetes comparing participants at the 80th vs the 20th percentiles were 3.58 for the level of total arsenic (95% CI, 1.18-10.83), 1.57 for dimethylarsinate (95% CI, 0.89-2.76), and 0.69 for arsenobetaine (95% CI, 0.33-1.48). CONCLUSIONS After adjustment for biomarkers of seafood intake, total urine arsenic was associated with increased prevalence of type 2 diabetes. This finding supports the hypothesis that low levels of exposure to inorganic arsenic in drinking water, a widespread exposure worldwide, may play a role in diabetes prevalence. Prospective studies in populations exposed to a range of inorganic arsenic levels are needed to establish whether this association is causal.

Cadmium exposure and all-cause and cardiovascular mortality in the U.S. general population.

Background: Urine cadmium concentrations were associated with all-cause and cardiovascular mortality in men in the 1988–1994 U.S. National Health and Nutrition Examination Survey (NHANES) population. Since 1988, cadmium exposure has decreased substantially in the United States. The associations between blood and urine cadmium and cardiovascular disease (CVD) mortality at more recent levels of exposure are unknown. Objectives: We evaluated the prospective association of blood and urine cadmium concentrations with all-cause and CVD mortality in the 1999–2004 U.S. population. Methods: We followed 8,989 participants who were ≥ 20 years of age for an average of 4.8 years. Hazard ratios for mortality end points comparing the 80th to the 20th percentiles of cadmium distributions were estimated using Cox regression. Results: The multivariable adjusted hazard ratios [95% confidence intervals (CIs)] for blood and urine cadmium were 1.50 (95% CI: 1.07, 2.10) and 1.52 (95% CI: 1.00, 2.29), respectively, for all-cause mortality, 1.69 (95% CI: 1.03, 2.77) and 1.74 (95% CI: 1.07, 2.83) for CVD mortality, 1.98 (95% CI: 1.11, 3.54) and 2.53 (95% CI: 1.54, 4.16) for heart disease mortality, and 1.73 (95% CI: 0.88, 3.40) and 2.09 (95% CI: 1.06, 4.13) for coronary heart disease mortality. The population attributable risks associated with the 80th percentile of the blood (0.80 μg/L) and urine (0.57 μg/g) cadmium distributions were 7.0 and 8.8%, respectively, for all-cause mortality and 7.5 and 9.2%, respectively, for CVD mortality Conclusions: We found strongly suggestive evidence that cadmium, at substantially low levels of exposure, remains an important determinant of all-cause and CVD mortality in a representative sample of U.S. adults. Efforts to further reduce cadmium exposure in the population could contribute to a substantial decrease in CVD disease burden.

Recent Changes in Breast Cancer Incidence in Spain, 1980–2004

Background Since the 1980s, Spain experienced two decades of sharply increasing breast cancer incidence. Declines in breast cancer incidence have recently been reported in many developed countries. We examined whether a similar downturn might have taken place in Spain in recent years. Methods Cases of invasive female breast cancer were drawn from all population-based Spanish cancer registries that had at least 10 years of uninterrupted registration over the period 1980–2004. Overall and age-specific changes in incidence rates were evaluated using change-point Poisson models, which allow for accurate detection and estimation of trend changes. All statistical tests were two-sided. Results A total of 80 453 incident cases of invasive breast cancer were identified. Overall age- and registry-adjusted incidence rates rose by 2.9% (95% confidence interval [CI] = 2.7% to 3.1%) annually during the 1980s and 1990s; there was a statistically significant change in this trend in 2001 (95% CI = 1998 to 2004; P value for the existence of a change point <.001), after which incidence declined annually by 3.0% (95% CI = 1.8% to 4.1%). This trend differed by age group: There was a steady increase in incidence for women younger than 45 years, an abrupt downturn in 2001 for women aged 45–64 years, and a gradual leveling off in 1995 for women aged 65 years or older. Separate analyses for registries that had at least 15 years of uninterrupted registration detected a statistically significant interruption of the previous upward trend in breast cancer incidence in provinces that had aggressive breast cancer screening programs and high screening participation rates, including Navarra (change point = 1991, P < .001), Granada (change point = 2002, P = .003), Bizkaia (change point = 1998, P < .001), Gipuzkoa (change point = 1998, P = .001), and Araba (change point = 1997, P = .002). Conclusions The recent downturn in breast cancer incidence among Spanish women older than 45 years is best explained by a period effect linked to screening saturation.

Arsenic in public water supplies and cardiovascular mortality in Spain

BACKGROUND High-chronic arsenic exposure in drinking water is associated with increased cardiovascular disease risk. At low-chronic levels, as those present in Spain, evidence is scarce. In this ecological study, we evaluated the association of municipal drinking water arsenic concentrations during the period 1998-2002 with cardiovascular mortality in the population of Spain. METHODS Arsenic concentrations in drinking water were available for 1721 municipalities, covering 24.8 million people. Standardized mortality ratios (SMRs) for cardiovascular (361,750 deaths), coronary (113,000 deaths), and cerebrovascular (103,590 deaths) disease were analyzed for the period 1999-2003. Two-level hierarchical Poisson models were used to evaluate the association of municipal drinking water arsenic concentrations with mortality adjusting for social determinants, cardiovascular risk factors, diet, and water characteristics at municipal or provincial level in 651 municipalities (200,376 cardiovascular deaths) with complete covariate information. RESULTS Mean municipal drinking water arsenic concentrations ranged from <1 to 118 microg/L. Compared to the overall Spanish population, sex- and age-adjusted mortality rates for cardiovascular (SMR 1.10), coronary (SMR 1.18), and cerebrovascular (SMR 1.04) disease were increased in municipalities with arsenic concentrations in drinking water > 10 microg/L. Compared to municipalities with arsenic concentrations < 1 microg/L, fully adjusted cardiovascular mortality rates were increased by 2.2% (-0.9% to 5.5%) and 2.6% (-2.0% to 7.5%) in municipalities with arsenic concentrations between 1-10 and >10 microg/L, respectively (P-value for trend 0.032). The corresponding figures were 5.2% (0.8% to 9.8%) and 1.5% (-4.5% to 7.9%) for coronary heart disease mortality, and 0.3% (-4.1% to 4.9%) and 1.7% (-4.9% to 8.8%) for cerebrovascular disease mortality. CONCLUSIONS In this ecological study, elevated low-to-moderate arsenic concentrations in drinking water were associated with increased cardiovascular mortality at the municipal level. Prospective cohort studies with individual measures of arsenic exposure, standardized cardiovascular outcomes, and adequate adjustment for confounders are needed to confirm these ecological findings. Our study, however, reinforces the need to implement arsenic remediation treatments in water supply systems above the World Health Organization safety standard of 10 microg/L.

Mortality risk during and after opioid substitution treatment: systematic review and meta-analysis of cohort studies

Objective To compare the risk for all cause and overdose mortality in people with opioid dependence during and after substitution treatment with methadone or buprenorphine and to characterise trends in risk of mortality after initiation and cessation of treatment. Design Systematic review and meta-analysis. Data sources Medline, Embase, PsycINFO, and LILACS to September 2016. Study selection Prospective or retrospective cohort studies in people with opioid dependence that reported deaths from all causes or overdose during follow-up periods in and out of opioid substitution treatment with methadone or buprenorphine. Data extraction and synthesis Two independent reviewers performed data extraction and assessed study quality. Mortality rates in and out of treatment were jointly combined across methadone or buprenorphine cohorts by using multivariate random effects meta-analysis. Results There were 19 eligible cohorts, following 122 885 people treated with methadone over 1.3-13.9 years and 15 831 people treated with buprenorphine over 1.1-4.5 years. Pooled all cause mortality rates were 11.3 and 36.1 per 1000 person years in and out of methadone treatment (unadjusted out-to-in rate ratio 3.20, 95% confidence interval 2.65 to 3.86) and reduced to 4.3 and 9.5 in and out of buprenorphine treatment (2.20, 1.34 to 3.61). In pooled trend analysis, all cause mortality dropped sharply over the first four weeks of methadone treatment and decreased gradually two weeks after leaving treatment. All cause mortality remained stable during induction and remaining time on buprenorphine treatment. Overdose mortality evolved similarly, with pooled overdose mortality rates of 2.6 and 12.7 per 1000 person years in and out of methadone treatment (unadjusted out-to-in rate ratio 4.80, 2.90 to 7.96) and 1.4 and 4.6 in and out of buprenorphine treatment. Conclusions Retention in methadone and buprenorphine treatment is associated with substantial reductions in the risk for all cause and overdose mortality in people dependent on opioids. The induction phase onto methadone treatment and the time immediately after leaving treatment with both drugs are periods of particularly increased mortality risk, which should be dealt with by both public health and clinical strategies to mitigate such risk. These findings are potentially important, but further research must be conducted to properly account for potential confounding and selection bias in comparisons of mortality risk between opioid substitution treatments, as well as throughout periods in and out of each treatment.

Metabolically Healthy Obesity and Development of Chronic Kidney Disease: A Cohort Study.

Context The risk for chronic kidney disease (CKD) among obese patients without metabolic abnormalities is unknown. Contribution In this cohort study of South Korean men and women, metabolically healthy overweight and obese participants had increased incidence of CKD compared with normal-weight participants. Caution Body mass index was a marker of obesity and was assessed only once at baseline. Implication Physicians should monitor metabolically healthy obese and overweight patients for CKD and counsel them about maintaining a healthy weight and lifestyle. Chronic kidney disease (CKD) is a major clinical and public health problem (1). It is a precursor for end-stage renal disease and a strong risk factor for cardiovascular morbidity and mortality (2). Its prevalence is increasing worldwide along with the growing prevalence of obesity and metabolic disease (3). Indeed, obesitymediated by hypertension, insulin resistance, hyperglycemia, dyslipidemia, and other metabolic abnormalitiesis a major risk factor for CKD (4). Although the role of obesity-induced metabolic abnormalities in CKD development is well-established, metabolically healthy obese (MHO) persons, seem to have a favorable profile with no metabolic abnormalities (5, 6). The association between MHO and CKD, however, is largely unknown. The only study available found no association (7), but the comparison between MHO and normal-weight participants could be biased because the reference group included overweight participants, and metabolically healthy participants were defined as those with fewer than 2 metabolic components. Therefore, we examined the association between categories of body mass index (BMI) and CKD in a large sample of metabolically healthy men and women who had health screening examinations. Methods Study Population The Kangbuk Samsung Health Study is a cohort study of South Korean men and women aged 18 years or older who had a comprehensive annual or biennial health examination at the clinics of the Kangbuk Samsung Hospital Health Screening Centers in Seoul and Suwon, South Korea (8). More than 80% of participants were employees of various companies and local governmental organizations and their spouses. In South Korea, the Industrial Safety and Health Act requires all employees to receive annual or biennial health screening examinations, offered free of charge. The remaining participants registered for the screening examinations on their own. Our analysis included all persons who had comprehensive health examinations from 1 January 2002 to 31 December 2009 and had at least 1 other screening examination before 31 December 2013 (that is, they all had a baseline visit and 1 follow-up visit [n=175859]) (Figure 1). We excluded persons who had metabolic abnormalities (5, 9, 10) or evidence of kidney disease at baseline (n=108263). We excluded those with fasting glucose levels of 100 mg/dL or greater or who used glucose-lowering agents; blood pressure (BP) of 130/85 mm Hg or greater or who used BP-lowering agents; triglyceride levels of 150 mg/dL or greater or who used lipid-lowering agents; high-density lipoprotein (HDL) cholesterol levels less than 40 mg/dL in men or less than 50 mg/dL in women; insulin resistance, defined as homeostasis model assessment of insulin resistance (HOMA-IR) scores of 2.5 or greater (11); estimated glomerular filtration rate (GFR) less than 60 mL/min/1.73 m2; proteinuria; history of CKD; or history of cancer. Among eligible participants (n=67596), we further excluded those with missing values in any of the study variables (n=5347 [7.9%]). The final sample size was 62249 participants (Figure 1), all of whom were metabolically healthy and did not have markers of kidney disease at baseline. This study was approved by the Institutional Review Board of the Kangbuk Samsung Hospital, which exempted the requirement for informed consent because we only accessed deidentified data routinely collected as part of health screening examinations. Figure 1. Study flow diagram. CKD = chronic kidney disease; HDL = high-density lipoprotein. * Participants in the screening program could have >1 criterion that made them ineligible for the study. Eligible participants could have missing data in >1 study variable. Measurements Data on medical history, medication use, family history, physical activity, alcohol intake, smoking habits, and education level were collected by a standardized, self-administered questionnaire. Anthropometry data, BP, and blood samples were obtained by trained staff during the examinations (8, 12). Smoking status was categorized as never, former, or current. Alcohol consumption was categorized as none, moderate (20 g per day), or high (>20 g per day). The weekly frequency of moderate- or vigorous-intensity physical activity was also assessed. Sitting BP, height, and weight were measured by trained nurses. Height was measured to the nearest 1 cm with a stadiometer while the participant stood barefoot. Weight was measured to the nearest 0.1 kg on a bioimpedance analyzer (InBody 3.0 and Inbody 720, Biospace), which was validated for reproducibility and accuracy of body composition measurements (13) and calibrated every morning before testing started. Body mass index was calculated as weight in kilograms divided by height in meters squared and was classified according to Asian-specific criteria (14) (underweight, BMI <18.5 kg/m2; normal weight, BMI of 18.5 to 22.9 kg/m2; overweight, BMI of 23 to 24.9 kg/m2; and obese, BMI 25 kg/m2). Blood specimens were sampled from the antecubital vein after at least a 10-hour fast. The methods for measuring serum levels of glucose, uric acid, total cholesterol, low-density lipoprotein (LDL) cholesterol, triglycerides, HDL cholesterol, aspartate aminotransferase, alanine aminotransferase, -glutamyltransferase, insulin, and high-sensitivity C-reactive protein (hsCRP) have been reported elsewhere (8, 12). The Department of Laboratory Medicine of the Kangbuk Samsung Hospital has been accredited by the Korean Society for Laboratory Medicine and the Korean Association of Quality Assurance for Clinical Laboratories and participates in the College of American Pathologists Proficiency Testing survey. Insulin resistance was assessed with the HOMA-IR equation (fasting insulin [uU/mL]fasting glucose [mmol/L] 22.5). An ultrasonographic diagnosis of fatty liver was defined as a diffuse increase of fine echoes in the liver parenchyma compared with the kidney or spleen parenchyma (15, 16). During the study period, serum creatinine levels were measured with the kinetic alkaline picrate method (Jaffe method) in an automated chemistry analyzer (from 2002 to 2009, we used the Advia 1650a Autoanalyzer [Bayer Diagnostics]; from 2010 to 2013, we used the Modular D2400 [Roche]). The within-batch and total coefficients of variation were 1.8% to 3.9% for low-level and 1.4% to 1.8% for high-level quality control specimens throughout the study. Because the laboratory method that was used to measure serum creatinine levels from 2002 to 2009 was not traceable to isotope-dilution mass spectrometry, we estimated GFR by using the 4-variable Modification of Diet in Renal Disease Study equation (17). The conclusions did not change if we used the Chronic Kidney Disease Epidemiology Collaboration equation (18) for GFR estimation (data not shown). Urine protein was measured semiquantitatively by urine dipstick (URiSCAN Urine test strips, YD Diagnostics) tested on fresh, midstream urine samples and was reported in the following 6 grades: absent, trace, 1+, 2+, 3+, and 4+ (corresponding to protein levels of undetectable, 10 mg/dL, 30 mg/dL, 100 mg/dL, 300 mg/dL, and 1000 mg/dL, respectively). Proteinuria was defined as a grade of 1+ or greater. Statistical Analysis Person-years of follow-up were calculated from the date of the baseline health examination until the date of CKD diagnosis or the last screening examination, whichever came first. The cumulative incidence of CKD for baseline BMI categories (<18.5, 18.5 to 22.9, 23.0 to 24.9, or 25.0 kg/m2) were standardized to the empirical distribution of baseline confounders in the overall study sample with inverse probability weighting (19, 20). We first fitted a multinomial logistic regression to estimate each participants probability of being in his or her own BMI category given the observed confounders. Stabilized weights were then calculated as the inverse of the estimated conditional probabilities of exposure, further rescaled by the overall proportion of participants in each BMI category to reduce variability of weights across groups and to avoid influential observations involving extremely obese persons (19). For risk analyses, we fitted a spline-based, parametric survival model (21) according to the stabilized weights and stratified by BMI category to obtain smooth estimates of the CKD cumulative incidence curves that would have been seen in the entire population if every participant had been in each category (20). This survival model parameterized stratum-specific log cumulative hazards as distinct natural cubic splines of log time with 3 internal knots at the 25th, 50th, and 75th percentiles; allowed for interval-censored events (incident CKD occurred at an unknown time point between the visit at which CKD was diagnosed and the previous visit); and used robust SEs for spline parameters that accounted for the correlation induced by weighting (21). For comparison, we also applied weighted KaplanMeier methods to estimate nonparametric cumulative incidence curves for each BMI category. We used the previously mentioned weighted, spline-based survival model to calculate adjusted differences in cumulative incidences of CKD at 2, 5, and 10 years of follow-up of normal-weight participants compared with those in the other BMI categories. We calculated 95% CIs by applying delta methods to the robust variance estimates of spline parameters. In addition to risk differences, we

Meta-analysis of folic acid supplementation trials on risk of cardiovascular disease and risk interaction with baseline homocysteine levels.

Experimental models and observational studies suggest that homocysteine-lowering therapy with folic acid (FA) may prevent cardiovascular disease (CVD). However, FA also stimulates cell proliferation and might promote progression of atherosclerosis. Our objectives were to perform a meta-analysis of FA supplementation trials on CVD events and to explore a potential interaction between FA supplementation and baseline homocysteine levels on CVD events. We searched MEDLINE for randomized controlled trials of FA supplementation to prevent CVD events (January 1966 to July 2009) and performed meta-analyses using random effects models. For trials that reported responses to FA supplementation stratified by baseline levels of homocysteine, we pooled within-trial estimates of differences in log-relative risks by baseline homocysteine levels using a random effects model. Overall, FA supplementation did not affect primary cardiovascular clinical end points (relative risk 1.02, 95% confidence interval [CI] 0.93 to 1.13, p = 0.66) or stroke (relative risk 0.95, 95% CI 0.84 to 1.08, p = 0.43). However, in trials that reported analyses stratified by baseline homocysteine, effect of FA supplementation differed by strata of baseline homocysteine (p for interaction = 0.030). Specifically, risks of primary clinical CVD events comparing FA supplementation to control were 1.06 (95% CI 1.00 to 1.13) in strata with mean baseline homocysteine levels >12 mumol/L and 0.94 (95% CI 0.86 to 1.03) in strata with baseline homocysteine levels <12 micromol/L. In conclusion, FA had no effect on CVD or stroke. However, analysis of within-trial results stratified by baseline homocysteine suggests potential harm in those with high homocysteine at baseline. This interaction may have important implications for recommendations of FA supplement use. In the meantime, FA supplementation should not be recommended as a means to prevent or treat CVD or stroke.

Effect of Supplementation With High-Selenium Yeast on Plasma Lipids: A Randomized Trial

BACKGROUND High selenium status has been linked to elevated blood cholesterol levels in cross-sectional studies. OBJECTIVE To investigate the effect of selenium supplementation on plasma lipids. DESIGN Randomized, placebo-controlled, parallel-group study stratified by age and sex. Participants, research nurses, and persons assessing outcomes were blinded to treatment assignment. (International Standard Randomised Controlled Trial Number Register registration number: ISRCTN25193534) SETTING 4 general practices in the United Kingdom. PARTICIPANTS 501 volunteers aged 60 to 74 years. INTERVENTION Participants received selenium, 100 mcg/d (n = 127), 200 mcg/d (n = 127), or 300 mcg/d (n = 126), as high-selenium yeast or a yeast-based placebo (n = 121) for 6 months. MEASUREMENTS Total and high-density lipoprotein (HDL) cholesterol concentrations were measured in nonfasting plasma samples stored from participants in the UK PRECISE (United Kingdom PREvention of Cancer by Intervention with SElenium) Pilot Study at baseline (n = 454) and at 6 months (n = 394). Non-HDL cholesterol levels were calculated. RESULTS Mean plasma selenium concentration was 88.8 ng/g (SD, 19.2) at baseline and increased statistically significantly in the treatment groups. The adjusted difference in change in total cholesterol levels for selenium compared with placebo was -0.22 mmol/L (-8.5 mg/dL) (95% CI, -0.42 to -0.03 mmol/L [-16.2 to -1.2 mg/dL]; P = 0.02) for 100 mcg of selenium per day, -0.25 mmol/L (-9.7 mg/dL) (CI, -0.44 to -0.07 mmol/L [-17.0 to -2.7 mg/dL]; P = 0.008) for 200 mcg of selenium per day, and -0.07 mmol/L (-2.7 mg/dL) (CI, -0.26 to 0.12 mmol/L [-10.1 to 4.6 mg/dL]; P = 0.46) for 300 mcg of selenium per day. Similar reductions were observed for non-HDL cholesterol levels. There was no apparent difference in change in HDL cholesterol levels with 100 and 200 mcg of selenium per day, but the difference was an adjusted 0.06 mmol/L (2.3 mg/dL) (CI, 0.00 to 0.11 mmol/L [0.0 to 4.3 mg/dL]; P = 0.045) with 300 mcg of selenium per day. The total-HDL cholesterol ratio decreased progressively with increasing selenium dose (overall P = 0.01). LIMITATION The duration of supplementation was limited, as was the age range of the participants. CONCLUSION Selenium supplementation seemed to have modestly beneficial effects on plasma lipid levels in this sample of persons with relatively low selenium status. The clinical significance of the findings is unclear and should not be used to justify the use of selenium supplementation as additional or alternative therapy for dyslipidemia. This is particularly true for persons with higher selenium status, given the limitations of the trial and the potential additional risk in other metabolic dimensions. PRIMARY FUNDING SOURCE The Cancer Research Campaign (now Cancer Research UK) and the University of Surrey.

Riesgo coronario atribuible a los factores de riesgo cardiovascular en población española

Introduccion y objetivos La carga de enfermedad coronaria atribuible a los factores de riesgo cardiovascular en Espana ha sido extrapolada tradicionalmente de otras poblaciones. Este estudio pretende estimar el riesgo coronario atribuible al tabaquismo, la hipercolesterolemia, la hipertension, la diabetes y el sobrepeso, utilizando datos procedentes de poblaciones Espanolas. Metodos Las prevalencias de los factores de riesgo en la poblacion general se obtuvieron de un metaanalisis de 48 estudios transversales realizados en Espana, y las prevalencias en enfermos coronarios se tomaron de los registros hospitalarios multicentricos PRIAMHO II y PREVESE II. Los riesgos relativos brutos y ajustados de enfermedad coronaria se obtuvieron del seguimiento durante 5 anos de una cohorte de atencion primaria de 6.124 personas adultas libres de enfermedad cardiovascular. Las fracciones atribuibles brutas y ajustadas se calcularon para ambos sexos y para varones y mujeres por separado. Resultados En los varones, el 42,5% (intervalo de confianza [IC] del 95%, 6,8%-59,6%) de la incidencia ajustada de enfermedad coronaria se atribuyo al sobrepeso; el 33,9% (IC del 95%, 22,6%-41%), al tabaquismo, el 19,4% (IC del 95%, 8,2%-26,5%), a la hipercolesterolemia, y el 15,5% (IC del 95%, 1,6%-24,6%), a la hipertension. En las mujeres, el 36,5% (IC del 95%, –8%-56,3%) de los casos de cardiopatia isquemica se atribuyeron al sobrepeso, el 24,8% (IC del 95%, 12%-31,9%), a la diabetes y el 20,1% (IC del 95%, 6,1%-28,6%), a la hipercolesterolemia. Conclusiones El sobrepeso y el tabaquismo en varones son los factores de riesgo cardiovascular a los que cabe atribuir un mayor impacto poblacional en la enfermedad coronaria.

Serum Selenium and Peripheral Arterial Disease: Results From the National Health and Nutrition Examination Survey, 2003–2004

The authors conducted a cross-sectional study of the association of serum selenium with the prevalence of peripheral arterial disease among 2,062 US men and women 40 years of age or older participating in the National Health and Nutrition Examination Survey, 2003-2004. Serum selenium was measured by using inductively coupled plasma-dynamic reaction cell-mass spectrometry. Peripheral arterial disease was defined as an ankle-brachial blood pressure index <0.90. The age-, sex-, and race-adjusted prevalence of peripheral arterial disease decreased with increasing serum selenium (P for linear trend = 0.02), but there was an indication of an upturn in risk in the highest quartile of serum selenium. The fully adjusted odds ratios for peripheral arterial disease comparing selenium quartiles 2, 3, and 4 with the lowest quartile were 0.75 (95% confidence interval: 0.37, 1.52), 0.58 (95% confidence interval: 0.28, 1.19), and 0.67 (95% confidence interval: 0.34, 1.31), respectively. In spline regression models, peripheral arterial disease prevalence decreased with increasing serum selenium levels up to 150-160 ng/mL, followed by a gradual increase at higher selenium levels. The association between serum selenium levels and the prevalence of peripheral arterial disease was not statistically significant, although a U-shaped relation was suggested.