Vitamin D status and hypertension: a review
Authors Ke L, Mason R, Kariuki M, Mpofu E, Brock K
Received 12 August 2014
Accepted for publication 26 November 2014
Published 8 April 2015 Volume 2015:8 Pages 13—35
Checked for plagiarism Yes
Review by Single anonymous peer review
Peer reviewer comments 2
Editor who approved publication: Dr Steven Atlas
Liang Ke,1 Rebecca S Mason,2 Maina Kariuki,3 Elias Mpofu,1 Kaye E Brock2
1Faculty of Health Sciences, 2Faculty of Medicine, University of Sydney, 3Biostatistical Officer Training Program, NSW Ministry of Health, Sydney, NSW, Australia
Abstract: Vitamin D is a steroid prohormone synthesized in the skin following ultraviolet exposure and also achieved through supplemental or dietary intake. While there is strong evidence for its role in maintaining bone and muscle health, there has been recent debate regarding the role of vitamin D deficiency in hypertension based on conflicting epidemiological evidence. Thus, we conducted a scoping systematic literature review and meta-analysis of all observational studies published up to early 2014 in order to map trends in the evidence of this association. Mixed-effect meta-analysis was performed to pool risk estimates from ten prospective studies (n=58,262) (pooled risk for incident hypertension, relative risk [RR] =0.76 (0.63–0.90) for top vs bottom category of 25-hydroxyvitamin D [25OHD]) and from 19 cross-sectional studies (n=90,535) (odds ratio [OR] =0.79 (0.73–0.87)). Findings suggest that the better the assessed quality of the respective study design, the stronger the relationship between higher 25OHD levels and hypertension risk (RR =0.67 (0.51–0.88); OR =0.77 (0.72–0.89)). There was significant heterogeneity among the findings for both prospective and cross-sectional studies, but no evidence of publication bias was shown. There was no increased risk of hypertension when the participants were of older age or when they were vitamin D deficient. Younger females showed strong associations between high 25OHD levels and hypertension risk, especially in prospective studies (RR =0.36 (0.18–0.72); OR =0.62 (0.44–0.87)). Despite the accumulating evidence of a consistent link between vitamin D and blood pressure, these data are observational, so questions still remain in relation to the causality of this relationship. Further studies either combining existing raw data from available cohort studies or conducting further Mendelian analyses are needed to determine whether this represents a causal association. Large randomized controlled trials are also needed to determine whether vitamin supplementation may be beneficial in the prevention or the treatment of hypertension.
Keywords: 25OHD, high blood pressure, meta-analysis, prospective, cross-sectional, blood pressure
Despite recent downward trends in cardiovascular disease (CVD) mortality rates,1 CVD still represents 50% of noncommunicable disease deaths worldwide,2 and there is an exponential increase in CVD incidence in lower- and middle-income countries.3 Hypertension, which is also increasing,4 is one of the primary modifiable risk factors for CVD, and as such, any new modifiable risk factor associated with prevention of this condition is important for public health measures. Obesity and lack of physical activity (PA) and increased salt intake are well-known and studied modifiable environmental factors associated with hypertension. In recent times, vitamin D deficiency has also been postulated to be such a factor.5–8
Vitamin D is a steroid prohormone synthesized in the skin following ultraviolet exposure. It is also achieved through supplemental or dietary intake. While there is strong evidence for its role in maintaining bone and muscle health,9 there has been recent debate regarding the role of vitamin D deficiency in CVD conditions10,11 based on conflicting epidemiological evidence.
There is a growing body of evidence from animal12 and clinical studies13 that vitamin D-mediated reduction of hypertension involves increased activation of the renin–angiotensin–aldosterone system, which is the main regulator of electrolyte and volume homeostasis that contributes to the development of arterial hypertension.
Epidemiologically, cross-sectional studies have consistently shown associations of hypertension with vitamin D deficiency as measured by the level of 25-hydroxyvitamin D (25OHD) (in nanomoles per litre) in the blood,7 and the most recent meta-analyses of prospective studies8 have also found this association to be persistent over time. However, meta-analysis results from randomized controlled trials (RCTs) (the gold standard of epidemiological studies) of 25OHD blood levels and hypertension have been null.14 This discrepancy may well be due to the small size and specialized population samples of the RCTs.
Due to the continued interest and debate in this area, we conducted a scoping systematic literature review and meta-analysis of all observational studies published up to early 2014 in order to map trends in the evidence on the association between blood vitamin D levels and the risk of hypertension.
For this systematic review, studies concerned with hypertension and 25OHD were identified using a predefined protocol and in accordance with Preferred Reporting Items for Systematic Reviews and Meta-Analyses (PRISMA) statement.15 Unlike previous reviews,7,8 we included studies that varied by culture of respondents for broader perspective (Supplementary material).
Data source and study search
We systematically conducted independent searches of Scopus and PubMed databases for published articles from January 1, 2007 until February 22, 2014. Identical search strategies were applied for each database search with combined terms of “25OHD”, “25-hydroxyvitamin D”, “vitamin D”, “hypertension”, “vitamin D supplementation (cholecalciferol [vitamin D3], ergocalciferol [vitamin D2])”, “systolic blood pressure (SBP)”, or “diastolic blood pressure (DBP)”. Reference lists of retrieved articles were automatically imported into Endnote X5 and manually scanned for relevant review articles. Duplicated references from two databases were detected by Endnote X5. In order to proceed further in the review process, retrieved articles’ abstracts were read by two independent reviewers (KB and LK). Only those abstracts that were related to 25OHD levels and hypertension were kept for full-text review and meta-analysis. Disagreements were resolved by a consensus or by reference with co-authors: statistician (MK) and/or vitamin D physiologist (RSM). We restricted the search to human studies and those published in English.
As a very recent meta-analysis has been published on RCTs,14 only observational (cross-sectional and prospective) studies were included in this meta-analysis. For these observational studies, the independent risk factor was plasma or serum vitamin D levels measured as 25OHD in blood, and the outcome was hypertension or SBP and DBP. Dietary vitamin D was not included in this systematic review. Figure 1 shows a flowchart of the data extraction.
Figure 1 Flowchart of meta-analysis data extraction.
We restricted this meta-analysis (Tables 1–4 and Figures 2A and 3A) to studies which recruited healthy adult study populations (aged greater than 18 years) from the general population. Prospective studies were included if they had at least 1 year of follow-up, with 25OHD levels measured at baseline, and if the results were reported categorically as a relative risk (RR) or an odds ratio (OR) with 95% confidence intervals (CIs).
Studies were excluded if the study sample was not recruited from the general population (ie, participants who had hypertension at baseline or participants with conditions that may influence vitamin D metabolism such as obese population groups16 or autoimmune diseases17). Exclusions applied as well if there was more than one study that investigated the same data (eg, The National Health and Nutrition Examination Survey (NHANES)18 duplicates were excluded).
Table 5 contains other extracted studies that reported associations with linear 25OHD levels. These studies were included in the systematic review results and discussion but not in the formal meta-analysis mapping.
Data extraction and quality assessment
The following data were extracted from each study:
- first authors’ last name, year of publication, study name, year of study conducted, and quality score;
- country of studies’ origin and study population;
- gender and age;
- sample size (number of cases of hypertension in the case of prospective studies);
- baseline 25OHD as either percent of vitamin D deficiency or mean of 25OHD and vitamin D assay method;
- 25OHD categories;
- mode of hypertension measurement;
- risk estimates (RRs or ORs) with corresponding CIs for blood 25OHD concentrations; and
- confounders measured and taken account for in analysis.
Study quality score was assessed based on the nine-star Newcastle–Ottawa Scale (NOS)10 using predefined criteria namely selection (population representativeness), comparability (adjustment for confounders such as age, gender, body mass index [BMI], PA, ethnicity, season, antihypertensive treatment, and diabetes status used), and ascertainment of outcome. In this predefined scoring method, a maximum of four points were given for selection, two points for comparability, and three points for outcome. Nine points on the NOS reflect the highest study quality.19
Data synthesis and analysis
Mixed-effect meta-analysis20 was performed to pool risk estimates for both observational and prospective studies. For both studies, we synthesized RR (for prospective studies) or OR (for cross-sectional studies), and 95% CI. These estimate compare the lowest vitamin D status as defined by categorical levels of 25OHD (as the reference group) to the highest vitamin D levels in order to estimate the risk of association with hypertension (primary endpoint).
Risk estimate values of less than 1.00 were associated with a decreased risk for hypertension as a result of increased blood levels of 25OHD. We performed sensitivity analyses to assess the influence of each individual study by removing one study at a time and calculating a pooled estimate for the remainder of the studies. No one study influenced the overall results, suggesting balanced selection.
We tested study heterogeneity by the I2 statistic (significance set at 95% level, ie, P<0.05).21 Potential publication bias was assessed by the Egger’s test and presented in a Begg’s funnel plot21 of standard mean differences against their standard error (Figures 2B and 3B). The meta-analysis procedure was conducted using Comprehensive Meta-Analysis, version 2.
Our initial search identified 970 potentially relevant citations (Figure 1). After screening of titles and abstracts, 89 articles remained for further evaluation. Following detailed assessment, 51 articles were excluded. Therefore, 38 studies were included in this study, but only 29 studies (ten prospective studies and 19 cross-sectional studies) were included in the formal meta-analysis; the other nine studies (one prospective study and eight cross-sectional studies) that reported linear results. In addition four studies which were prospective studies and one cross-sectional study, which also reported linear results, are included in Table 5.
Characteristics of included studies – prospective studies
The pooled RR (95% CI) for incident hypertension (primary endpoint) in a comparison of individuals in the top category of 25OHD levels with lowest category (as reference group) of 25OHD levels was 0.76 (0.63–0.90) (Figure 2A).
There was evidence of heterogeneity among the findings of the studies that measured blood 25OHD levels (I2=67.05, P<0.01). The Egger’s test based on all included studies showed no evidence of publication bias for blood 25OHD concentrations and hypertension (P=0.53), with the funnel plot shown in Figure 2B.
Overall, we identified eleven prospective studies,22–32 of which ten have been included in this formal meta-analysis.22–31 One study by Skaaby et al32 from Denmark only reported a linear association between 25OHD and blood pressure and as such, was not included in the formal meta-analysis but is reported in Table 5. In summary, Table 1 presents ten prospective studies with aggregate data on 58,262 nonoverlapping participants and 8,213 incident hypertension cases as potentially relevant for the present meta-analysis.
Thus, Table 1 and Figure 2A include two cohort studies24,25 and eight prospective studies,22,23,26–31 which were cohort studies in design but only reported baseline 25OHD levels and subsequent future hypertension incidence.
Of these ten studies, two studies25,30 also reported baseline as well as follow-up cross-sectional categorical data from the same cohort data, which were included in the cross-sectional meta-analysis (Tables 3 and 4). Four other studies reported baseline 25OHD data in linear format from these cohorts,23,26,27,29 and these data are reported in Table 5.
Table 1 provides details of the eligible studies that evaluated vitamin D status and the RRs of hypertension incidence. Six studies22–24,27,29,31 were carried out in the US, two studies were conducted in Europe,25,30 and two26,28 were conducted in the Asia Pacific region including Australia.28 Most of the study samples were from general populations.23–28,30,31 In two studies, populations were recruited from nurses, health professionals, or physicians22,29 and in one study, the population were male smokers.30 The age of participants ranged from 25 years to 85 years (mean age =55 years), and more than half of the studies22,24–26,28,31 sampled included both male and female. Ascertainment of hypertension was mostly by measuring blood pressure,23–28,30,31 and the follow-up period ranged from 1.3 years to 15 years. Table 1 also provides assay characteristics of measured levels of 25OHD from studies contributing to the analyses; five studies22,23,28–30 used the radioimmunoassay (RIA) method, four24–27 used the chemiluminescence immunoassay (CLIA), and only one31 used the gold standard “high-pressure liquid chromatography” (HPLC) analysis.
Vitamin D status and risk of hypertension – prospective studies subgroup analysis
When studies were stratified by quality score, the RRs were significant for studies rated higher than 5 (RR =0.67 (0.51–0.88)) but were not significant for studies rated ≦5 (RR =0.86 (0.71–1.05)). There was no statistically significant heterogeneity among studies rated higher than 5 (I2=37.62, P>0.05), but significant heterogeneity was found among studies rated ≦5 (I2=68.67, P<0.05). Detailed results when studies were stratified by demographic factors (age, gender, country region, and ethnicity), vitamin D factors (vitamin D levels, season, assay methods), hypertension (measured or self-report, history of anti-hypertensive use), and confounders (BMI, PA, and diabetes status) are given in Table 2 and Figure 2A–D.
Characteristics of included studies – cross-sectional studies
The pooled OR-estimated risk of hypertension (primary endpoint) for the highest vs the lowest category of blood 25OHD concentrations was 0.79 (0.73–0.87) (Figure 3A). There was statistically significant heterogeneity among all cross-sectional studies (I2=45.37, P<0.05). The Egger’s test based on all included studies showed no evidence of publication bias for blood 25OHD concentrations and hypertension (P=0.62), together with the funnel plot shown in Figure 3B.
Twenty-seven cross-sectional studies were identified, of which 1925,30,33–49 were included in this formal meta-analysis (Tables 3 and 4 and Figure 3A). Of these 19 cross-sectional studies, one study48 also reported linear results that are reported in Table 5. The remaining extracted cross-sectional studies only reported 25OHD estimates in linear fashion and thus were not included in the formal meta-analysis but are reported in Table 5.29,48,50–57
In summary, Tables 3 and 4 represent 19 cross-sectional studies with aggregate data on 90,535 nonoverlapping participants. Tables 3 and 4 provide details of the eligible studies that evaluated vitamin D status and the ORs of hypertension. Six studies were carried out in the US,33,34,36,41,43,44 five studies in Europe,25,30,35,37,40 five studies in the Asia Pacific38,39,46–48 (including one in Australia39), one in Middle-East,42 one in Puerto Rico,45 and one in South Africa.49 Sixteen studies were recruited from the general population,37–44,46,48,49 and two studies were sampled from either clinic attendees45 or factory employees.47 The age of participants ranged from 18 years to 92 years, and only five studies were of one gender,30,36,39,40,49 and the majority were mixed. Ascertainment of hypertension was mostly by measuring blood pressure and in only two studies,36,44 it was from self-report.
Tables 3 and 4 also provides assay characteristics of measured levels of 25OHD from studies contributing to the analyses. Nine cross-sectional studies30,33,38,39,41,42,44,47,48 used the RIA method, six cross-sectional studies used CLIA or electro-chemiluminescence immunoassay,25,34–36,45,46 one used enzyme-linked immunosorbent assay,37 one used Nichols Advantage,43 one used Roche Elecsys,49 and one used HPLC40 for blood 25OHD analyses.
Vitamin D status and risk of hypertension – cross-sectional studies subgroup analysis
When studies were stratified by quality score, the ORs were significant for studies rated 5 (OR =0.71 (0.61–0.83)) and 6 (OR =0.79 (0.73–0.87)) but were not significant for studies rated ≦4 (OR =0.87 (0.75–1.01)). There was no statistically significant heterogeneity among studies rated at 4 (I2=46.13, P>0.05), 5 (I2=39.34, P>0.05), or 6 (I2=0.00, P>0.05). Detailed results when studies were stratified by demographic factors (age, gender, country region, and ethnicity), vitamin D factors (vitamin D levels, seasons, and assay methods), hypertension (measured or self-report, history of anti-hypertensive use), and confounders (BMI, PA, and diabetes status) are given in Table 4 and Figure 3A–D.
Physiology of vitamin D
In humans, vitamin D is normally obtained from skin through the action of ultraviolet B irradiation on 7-dehydrocholesterol.58 It is further metabolized to 25OHD, the major circulating vitamin D compound, and then to 1,25-dihydroxyvitamin D (1,25D), the hormonal form.4–6,9 The major function of vitamin D compounds is to enhance active absorption of ingested calcium (and phosphate). This assists in building bone at younger ages and ensures that bone does not need to be resorbed to maintain blood calcium concentrations. As there are vitamin D receptors in most nucleated cells, including vascular smooth muscle cells, as well as in macula densa and juxtaglomerular cells,59,60 vitamin D compounds appear to have direct effects to improve bone and muscle function, and there is good, though not entirely consistent, evidence that supplemental vitamin D and calcium together reduce falls and fractures in older individuals.61 Based on calcium control and musculoskeletal function, target levels of 25OHD in blood are at least 50–60 nmol/L, and there may be a case for higher targets of 75–80 nmol/L.10,11
Summary and comparison with other meta-analyses
The overall results from this recent meta-analysis and systematic review are that from a total of 148,797 healthy participants (58,262 prospective; 90,535 cross-sectional) from general population samples across the world (published between 2007 and early 2014), lower 25OHD levels appear to be associated with increased hypertension levels (prospective analyses: RR =0.76 (0.63–0.90); cross-sectional analyses: OR =0.79 (0.73–0.87)). These updated results report similar findings published by Kunutsor et al for prospective studies in 2013 (RR =0.70 (0.58–0.86))8 and for cross-sectional studies by Burgaz et al in 2011 (OR =0.73 (0.63–0.84)).7
In addition, our systematic review of 172,259 participants and 38 studies concurs with observations from the above meta-analyses in that 60% of studies reported a significant inverse association between blood 25OHD and hypertension. Of these, 40% were reported from prospective studies (Table 1), 56% from cross-sectional studies (Table 3), and 64% from those studies that reported linear associations of 25OHD with hypertension (Table 5).
It should be noted that mostly these effects were of a small magnitude and have not been confirmed in results from RCTs.14 Probably, because of these facts and other even less-convincing data from mortality studies62,63 and other CVD outcomes,4–6,9 critics have hypothesized that observational associations may be due to an association between low vitamin D and general “ill health”,64 a conclusion observational studies cannot fully address due to their study design. Thus, the major criticism of observational studies is that results may be due to reverse causality (such as already unwell participants) and/or unmeasured bias or confounding (such as obesity and lack of PA), which RCTs attempt to take into account by randomization. This review has attempted to address some of these issues by stratification and sensitivity analyses.
Quality of included studies
When prospective studies were stratified by the journal quality ratings score (≥6 vs lower),19 the association between low 25OHD and increased hypertension was both significant and not heterogeneous in the better-quality studies23–26,28 (score ≥6, RR =0.67 (0.51–0.88); score <6, RR =0.86 (0.71–1.05)) (Figure 2C). A similar pattern occurred in cross-sectional studies, although the effect was not quite as marked in that all the studies remained significant in their category and also had no heterogeneity, but the “higher quality”33,35,40,41 studies showed a stronger association between lower 25OHD levels and hypertension vs “moderate quality”34,37–39,43,48 (score =6, OR =0.79 (0.73–0.87); score =5, OR =0.72 (0.65–0.80); score =4, OR =0.86 (0.80–0.93)) (Figure 3C).
Heterogeneity and publication bias
As with the previous meta-analyses, there was no publication bias reported, probably due to the strict criteria used for selecting the studies to be used. However, in contrast to the two previous meta-analysis,7,8 which reported no heterogeneity in their results, this present meta-analysis reported heterogeneity among studies of blood 25OHD concentrations and hypertension (in both prospective and cross-sectional studies) (Tables 2 and 4). The previous meta-analyses restricted their study selection to defined populations (eg, primarily Caucasian from either Europe or the US). The heterogeneity reported in the present meta-analysis is probably due to the wide scope of the literature search in demographic range (age, gender, country location, and ethnicity) of the studies assessed and also the different 25OHD assay technologies used.
Demography and ethnicity
The age range in this review was 18–96, and the effect of low 25OHD on hypertension remained significant in both younger and older strata and somewhat surprisingly, was markedly stronger in those aged <55, and in females in prospective and cross-sectional data (Figures 2D and 3D).
When it was possible to investigate gender separately, heterogeneity disappeared in both prospective and cross-sectional studies, but the associations became nonsignificant in the prospective studies, probably due to lower sample sizes. Females did seem to have a greater degree of association of hypertension risk with low vitamin D, especially at a younger age. This is puzzling as one would not expect younger females to have increased risk of hypertension, but increasingly younger females are being reported to be at risk for vitamin D deficiency, particularly in Asian populations.65 These findings need to be further investigated; our recent data from Macau also confirm this risk in younger women.66,67
When investigated by region or country of the study population, countries from Europe and the US were more similar (ie, less heterogeneity) than those from other regions of the world; previous meta-analyses have concentrated on these countries. In this meta-analysis, the effect of vitamin D deficiency on hypertension was attenuated in the European studies compared to the total risk estimate and was, in fact, non-significant from prospective data. When ethnicity was investigated, those of “multi-ethnic group” ethnicities did not show an effect compared with others; as Burgaz et al7 noted, there is evidence that vitamin D synthesis is less efficient among individuals with greater skin pigmentation,68,69 but variations in culturally preferred covering of skin by clothing could also be an explanation for these findings.70 More studies in different cultures are needed to disentangle these findings.
Measurement of blood pressure variables
Only three studies included in the present meta-analysis have used self-reported hypertension as outcomes (two in prospective22,27 and one in cross-sectional44), which can only give a crude estimate of average blood pressure. In our stratified analysis, the effect was attenuated when studies took account of measured blood pressure, but the negative association between decreased 25OHD and hypertension remained significant. In addition, taking into account the use of antihypertensive treatments is an important confounder; two prospective studies22,30 and five cross-sectional studies30,36,44,47,49 did not have this variable; in our stratified analysis, the effect was attenuated when studies took account of antihypertensive medication, but the negative association between decreased 25OHD and hypertension remained significant, and in addition, studies which took account of blood pressure medications did not have heterogeneity.
Measurement of 25OHD levels
There has been debate over the measurement of 25OHD in blood samples and its variability.58 HPLC has been considered the “gold standard” but as can be seen in the present stratifications, RIA was by far the most commonly used method. There were differences between these methods, which could well explain some of the heterogeneity detected in our meta-analyses. A recent paper has reported good similarity between these various methods,71 and with the exception of HPLC, all assay methods produced significant associations.
Season of blood draw and measurement of 25OHD
It is well established that 25OHD concentrations and hypertension are associated with season.72,73 When studies that adjusted for season were compared with studies that did not take seasonality into account (usually by date of draw of the blood samples), the association between low 25OHD and hypertension risk remained significant. Only one prospective study22 did not adjust for season, and in cross-sectional studies, most studies appear to have taken season into account30,33–40,44,46 but not others. In our stratification analysis, taking season into account did reduce the effect size but not significance.
Deficiency vs sufficiency of vitamin D status
There has been some discussion that the effect of 25OHD on hypertension risk may be more potent in those who are originally vitamin D deficient vs sufficient.7,8,27 The opposite effect was seen in these data in that a significant effect was only seen in those who had sufficiency, not deficiency, although it should be pointed out that the deficiency studies were fewer in number and in size. In addition, when those who were older and had deficiency were investigated in prospective studies, the effect became nonsignificant and attenuated in cross-sectional studies (87% of total data).
Confounding by healthy lifestyle variables
It has been suggested that confounding by health lifestyle variables may account for the associations seen between higher 25OHD and less hypertension.64 In particular, BMI, as a marker of obesity, is an independent risk factor for both vitamin D deficiency74–77 and hypertension.78–83 In fact, earlier investigators did not adjust for BMI in their hypertension and 25OHD analyses as they considered it to be a mediating factor and part of the causal chain.50 More recently, Mendelian analysis has confirmed that obesity is a “cause” of vitamin D deficiency, not the other way around,84 and recent studies have inferred that the effect of BMI may be due to a body dilution effect.85 In this analysis, only 15% of studies (five) did not adjust for BMI, and adjustment did make the associations smaller in effect; they nevertheless remained significant. Thus, two recent Mendelian randomization studies investigating the relationship between adiposity and vitamin D concentrations have confirmed this important mediating effect of obesity and vitamin D.84,86
Potential mechanisms of action to explain a protective effect of vitamin D in hypertension
As we have summarized above, there are a number of confounding mechanisms, which could explain an association between low 25OHD concentrations and high blood pressure. In particular, being overweight or obese is known to be linked to low vitamin D concentrations and to higher readings for blood pressure using a normal sphygmomanometer cuff.87,88
There are also a number of plausible physiological mechanisms to explain why low vitamin D status might lead to elevated blood pressure. The active hormone of vitamin D, 1,25D, has been shown to decrease the expression of the renin gene through a vitamin D receptor-dependent mechanism, thus decreasing both renin and angiotensin II concentrations.89,90 This mechanism results in hypertension in mice, in which the capacity to produce 1,25D is knocked out,90 or in mice that lack the vitamin D receptor.89 A negative association between 25OHD, 1,25D concentrations, and plasma renin activity in patients with hypertension has been reported91 and in patients with chronic heart failure, a short course of vitamin D treatment resulted in a significant decrease in plasma renin activity and concentration.92 Vitamin D deficiency also results in higher than normal concentrations of PTH. High levels of PTH have long been associated with elevated blood pressure, reversed by parathyroid gland removal in mice,93 while treatment of older female normotensive women with vitamin D and calcium reduced blood pressure and parathyroid hormone, more effectively than calcium alone.94 There is also considerable evidence from both animal and human studies that the vitamin D system affects vascular endothelial function in several ways, including affecting vascular stiffness, oxidative stress, and through upregulation of endothelial nitric oxide syntheses.95–99
Our study also has several strengths and limitations as do all meta-analyses of observational studies.
Inadequate control for confounders may bias the results in either direction, toward exaggeration or underestimation of the estimates, as such residual or unknown confounding cannot be excluded as a potential explanation for the observed findings. In this analysis, stratification has attempted to answer some of these concerns (Tables 2 and 4).
As was the case with Kunutsor et al,8 it was not possible to correct the estimates for within-individual variation in vitamin D levels over time or across seasons, because data involving repeat measurements were not reported. Although there are reports that 25OHD exhibits low within-individual variability (r2=0.87 between measured 25OHD levels after several years),100,101 studies are still needed with serial measurements of vitamin D.
Another limitation is that 19 of the studies included had a cross-sectional design, which cannot exclude the possibility of reverse causality.
Despite the general nature of these cohorts, it must be noted that our and any other study investigating 25OHD levels are only reporting on those who gave blood, not the entire cohort (average response rate =65%).
Though the meta-analysis was very comprehensive, it was, as are all meta-analyses based on data from published reports, preventing the undertaking of adjustment for confounding and assessment of potential interactions. As has recently been discussed, meta-analyses are only as accurate as the veracity of included data.102 Thus, collaborative pooling of individual participant data from cohort studies should be conducted for more detailed analyses under a broader range of circumstances as has been done in recent Mendelian analyses.84,103
In this analysis, ten prospective studies, which are better at being able to determine the role of blood 25OHD concentrations in the cause of hypertension, were included. Most of the studies in this meta-analysis were designed to specifically investigate the effect of blood 25OHD concentrations on the risk of hypertension in a general population. Twenty-two studies had as the main focus hypertension and the other seven had metabolic syndrome or heart diseases. More cohort studies specifically designed to investigate this question are needed with long follow-up time as the study by Jorde et al25 has presented.
This is the largest meta-analysis of both prospective and cross-sectional associations conducted to date (excluding data from dietary studies and nested case–control studies) and provides precise estimates of the magnitude of the association of hypertension risk with vitamin D levels.
This present meta-analysis included studies that had recruited participants from mainly general populations, therefore reducing any effects of clinically evident preexisting disease on vitamin D levels.
In this meta-analysis, the eligible studies were carried out in many study sites and countries, which enhances generalization of our findings. Despite the general nature of these cohorts, it must be noted that our and any other study investigating 25OHD levels are only reporting on those who gave blood, not the entire cohort (average response rate =65%, ranging from 10% to 100%).
As with any meta-analysis of published studies,7,8 publication bias is of concern as small studies with null results tend not to be published; however, in both prospective and cross-sectional studies, there was no evidence of publication bias.
Sensitivity and stratification analysis conducted with these data attempted to examine the impact of known hypertension risk factors and 25OHD confounders.
Findings from our review suggest the possibility of a causal relationship, but establishing this requires robust evidence from other study designs such as clinical trials and Mendelian analyses. Mendelian analysis may shed light on whether vitamin D could be directly causal in hypertension risk. A large percentage of the variability in 25OHD levels is explained by genetic factors. Heritability of 25OHD levels has been estimated to be as high as 80%. The reason for the advantages of Mendelian randomization is that individual genotypes are assigned randomly at meiosis; thus, the effect of genetics on diseases is generally unaffected by confounding or reverse causality. Two genotypes CYP2R1 and CHCR7 have been found to function upstream of 25OHD production and affect the vitamin D metabolic system and subsequent substrate availability.103 These genotypes affect vitamin D metabolism as proxy markers for lifelong differences in vitamin D status. Thus Vimaleswaran et al103 in a Mendelian analysis of 108,173 individuals from 35 studies used these genetic variables to test for a causal association with blood pressure and hypertension, which showed that each 10% increase in genetically instrumented plasma 25OHD concentration was associated with a significant 8% reduced odds of hypertension (OR =0.92 (0.87–0.97)) as well as reduced SBP (P=0.003) and DBP (P=0.01).
However, there is still a need to see what dosages of 25OHD affect hypertension risk via RCTs, and as mentioned previously, the most recent meta-analysis of vitamin D supplementation and hypertension has observed no evidence to support an effect of vitamin D supplementation on hypertension risk. Many of the RCTs are small studies on specialized subjects (often from clinics), and there are large differences in duration and doses of 25OHD.14 As many commentators have urged,9–12,62,63,104 there is a need for carefully designed large RCTs with long-term treatment with optimum vitamin D dosages on blood pressure. The recent and continuing Vitamin D and OmegA-3 TriaL (VITAL), an RCT of 20,000 US men and women >50 years, is investigating whether taking daily supplements of vitamin D3 reduces the risk of CVDs in people without prior history of these diseases, which may help disentangle and clarify this situation.105
Despite the evidence of a consistent link between vitamin D and blood pressure, questions still remain in relation to the causality of this relationship. Findings from this systematic literature review suggest the possibility of a causal relationship, but several RCTs have attempted to address these questions but with inconsistent results. Further studies either combining and re-analyzing existing data from available cohort studies or conducting further Mendelian analysis are needed to determine whether this represents a causal association. In addition, large RCTs are needed to determine whether vitamin supplementation or therapy may be beneficial in the prevention or the treatment of hypertension.
RSM receives speaker fees from Amgen Pty Ltd and AbbVie Australia. The other authors report no conflict of interest in this work.
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Abbreviation: PICOS, participants, interventions, comparisons, outcomes, and study.
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