Restless legs syndrome (RLS) is a common sleep disorder, with an estimated prevalence of 5 to 10% of the adult population.1–3 RLS is defined as an urge to move the legs when resting or lying down, especially at night, that is relieved by activity.1 The pathophysiologic basis of RLS is poorly understood. Previous studies have identified a variety of both central and peripheral nervous system abnormalities in patients with RLS. Regarding central nervous system factors, the most consistent risk factor linked to RLS is reduced central iron stores, even in the setting of normal systemic iron studies, suggesting a perturbation in homeostatic mechanisms that regulate the iron influx and/or efflux from the cell.4 Likewise, alterations in dopaminergic systems, likely attributed to an increased dopamine turnover in RLS;5 and circadian disruption with increased circadian dopaminergic variation,6, 7 are also plausible mechanisms. Regarding peripheral nervous system, hyperalgesia characterized by elevated pinprick pain rating scores in the legs, has been associated with central sensitization to A-delta fiber high-threshold mechanoreceptor input, a characteristic sign of the hyperalgesic neuropathic pain present in RLS.4
The most common comorbid conditions associated with RLS include systemic iron deficiency (low serum ferritin levels <50 mcg/L and subsequent low central nervous system intracellular iron),8 renal failure with uremia, frequently associated with periodic limb movements of sleep indices,9 neuropathy,10 spinal cord pathology,11 pregnancy,12 multiple sclerosis,13 Parkinson´s disease and essential tremor.14,15 RLS is a treatable condition, that generally responds well to pharmacologic treatment including iron therapy and non-ergot dopamine agonists or alpha-2-delta calcium channel ligands, as the first line therapy, concurrent with avoidance of mental alerting activities, and stimulant substances like caffeine.
A growing body of evidence relates RLS to an increased risk of mortality attributable to both cerebrovascular and cardiovascular events,16,17 likely mediated by sympathetic hyperactivity,18 or linked to other chronic conditions (e.g., obesity, depression, and disability).19–22 However, this relationship has not been confirmed by others.23–25 Assessment and identification of RLS as a modifiable mortality risk factor carries important public health implications and suggests the need for RLS screening and monitoring. The aim of this study was to quantitatively review the association between RLS and global mortality according to the results of eligible independent cohort studies.
Search strategy and meta-analysis followed the PRISMA guidelines.26 We searched the PubMed database using the search terms “mortality,” “survival” and “RLS,” and “Willis–Ekbom disease.” The search was restricted to English and Spanish language articles involving human subjects, reviews, and meta-analysis, and prospective studies, in which these terms appeared in the title or abstract, and were published between January 1, 1950 and January 15, 2019. We also reviewed cross-references of selected publications for added perspective. In the meta-analysis, we only included prospective observational studies reporting regression analysis and hazard ratios (HR) for mortality with 95% confidence interval (CI). We excluded all case reports and observational studies not providing the aforementioned HR.
All relevant articles were independently evaluated by all of the authors, and disagreements were resolved by consensus. Data extracted from each study included first author, year of publication, population, number of participants, type of study design, criteria for RLS diagnosis, HR (95% CI) for mortality, possible confounding variables, advantages, and disadvantages.
HR for mortality of each selected study was recorded and presented in a forest plot graph. A pooled HR with a 95% CI was calculated based on data extracted from each study. A random-effects DerSimonian Laird model and the Galbraith plot were used to calculate the pooled effect estimates.27 We assessed heterogeneity between studies using the Cochran’s Q and I2 statistics, and statistical significance was considered with a p-value <0.001. For the qualitative interpretation of heterogeneity between studies, the funnel plot inspection28 and the Begg’s and Egger’s statistical tests29 were performed. Epidat version 3.1 software (Servicio Gallego de Salud, Spain) was used for statistical analysis.
An initial screening of the papers yielded 68 articles eligible for analysis. After excluding non-longitudinal studies and those not matching the inclusion criteria, a total of 13 studies were finally selected and included in the meta-analysis (Figure 1). Table 1 shows the main features of the studies including the sample size; population type including general community versus end-stage renal disease, gender; RLS assessment criteria; HR (95% CI) for mortality as the primary outcome measure; covariates included in each multivariate Cox regression analysis; and the strengths and weaknesses of each study. Figure 2 shows the Forest Plot graph of eligible studies. The diagnosis of RLS was established using the International Restless Legs Syndrome Study Group (IRLSSG) diagnostic criteria30 in five studies (35.7%).31–35 In nine studies (64.3%), the diagnosis of RLS was based on self-administered questionnaires,4,36–38 ICD-9 codes,5,39 and other sleep quesionnaires.40,41 The results of 11 studies (78.6%)4,5,31–34,36,37,40,41 supported RLS as a risk factor for increased mortality. The opposite conclusion was found in only three studies (21.4%).35,38,39
|Study||Population (n)||Follow-up (years)||RLS assessment||Outcome hazard ratio (95% CI)||Confounding factors adjustment||Disadvantages||Disadvantages|
|Pollak, et al.38||Elderly community-based population (1,885)||3.5||Self-administered sleep questionnaire||Females:1.36 (0.94–1.96) Males: 0.92 (0.60–1.42).||Age, Activities of daily living (ADL) problems, self-assessed health, income, cognitive impairment, depression, living alone, insomnia||The first prospective study analyzing survival in RLS urban-based community||Limited RLS diagnostic accuracy|
|Winkelman et al.36||End-stage renal disease-based population (204)||2.5||Self-administered sleep questionnaire||1.85 (1.12–3.07)||Age, sex, number of years of dialysis||Large sample and novel information (independent association of RLS with discontinuation of dialysis)||Clinic-based sample, limited RLS diagnostic accuracy|
|Unruh et al.37||Dialysis-based population (894)||3||Self-administered sleep questionnaire||1.39 (1.08–1.79)||Age, race, sex, dialysis mode, insulin-requiring diabetes, comorbidity and Karnofsky indexes, and center||Inclusion of patients with other types of dialysis, ethnic populations, and treatments information||Limited diagnostic accuracy|
|Molnar et al.31||Kidney-transplantation recipients-based population (804)||4||RLS questionnaires||2.02 (1.03–3.95)||Diabetes, arterial hypertension, transplantation vintage, glomerular filtration rate, serum albumin, hemoglobin, C-reactive protein||Large sample size, novel information (association of RLS with kidney transplant recipients),||Limited information on cardiovascular confounders, selection bias due to high proportion of missing data (25%)|
|Mallon et al.40||Community-based population (5,102)||20||Upsala Sleep Inventory||Females:1.85 (1.20–2.85) Males:0.81 (0.51–1.28)||Age, short nigh sleep time, lifestyle factors (living alone), medical conditions such as smoking, habitual snoring, BMI ≥ 30, hypertension, heart disease, diabetes, asthma, and depression||Community-based population, large sample size, high response rate||Limited diagnostic accuracy, lack of information on treatments|
|La Manna et al.32||End-stage renal disease patients on dialysis-based population (100)||1.5||RLS Study Group diagnostic criteria||6.29 (1.74–22.79)||Age, gender, BMI, comorbidity index, albumin, residual diuresis||Novel information (need of phenotyping intermittent vs. continuous RLS and inflammatory markers)||Limited follow-up|
|Li et al.33||Community-based population (18,425)||8||RLS diagnostic index||Men:1.92 (1.03–3.56)||Age, ethnicity, body mass index, life style factors (smoking, alcohol, and physical activity), chronic conditions (cancer, hypertension, cardiovascular disease and other comorbidities), sleep disorders and duration||Large sample size and exclusion of RLS mimics||Selection bias (relatively healthy Caucasian male population with access to health care)|
|Lin et al.34||End-stage renal disease patients-based population (1,093)||3||RLS diagnostic index||1.53 (95% CI 1.07–2.18)||Age, sex, duration of dialysis, comorbidity of diabetes mellitus, comorbidity of hypertension, serum hemoglobin level, transferrin saturation, serum iron level, and the numbers of cardio-/cerebrovascular events||Large survey of RLS in dialysis patients, inclusion of clinical laboratory data, and medical record review|
|Stefanidis et al.35||End-stage renal disease-based population (579)||3||RLS Study Group diagnostic criteria||0.66 (0.41–1.06)||Age, sex, diabetic nephropathy, duration of dialysis, dialysis mode, body mass index, serum urea before hemodialysis (HD), urea reduction ratio, Kt/V, β2-microglobulin, C-reactive protein, albumin, hemoglobin, serum iron, ferritin, transferrin, transferrin saturation, calcium, phosphorus, parathyroid hormone||Large sample size, RLS diagnostic accuracy||Lack of information on mortality ascertainment and kidney transplantation during follow-up|
|Molnar et al.5||Community-based population (3,000,000)||8||ICD-9 code||1.88 (1.70–2.08)||Age, gender, race/ethnicity, income, marital status, baseline estimated glomerular filtration rate, comorbidities at baseline (diabetes, hypertension, cardiovascular disease, heart failure, cerebrovascular disease, peripheral vascular disease, lung disease, dementia, rheumatic disease, malignancy, HIV/AIDS, depression, presence of obstructive sleep apnea and presence of periodic limb movements in sleep, and BMI||Large sample size, and event numbers||Limited RLS diagnostic accuracy Use of propensity score method|
|Ricardo et al.41||Non-institutionalized community-based population (1,470)||3||Sleep Hear Health Study Habits Questionnaire and Functional Outcomes of Sleep Questionnaire||1.69 (1.04–2.75)||Diabetes, hypertension, tobacco, hypnotic consumption, congestive heart failure, depression, BMI, age, sex, race, ethnicity, income, glomerular filtration, and albuminuria||Large sample size and follow-up||Limited diagnostic accuracy, exclusion of subjects with missing creatinine/urine albumin data|
|DeFerio et al.39||End-stage renal disease patients on dialysis-based population (1,456,114)||2||ICD-9 code 333.94||1.16 (0.88–1.44)||Age, sex, race, ethnicity, vascular access type, BMI, serum albumin level, coronary artery disease, congestive heart failure, cerebrovascular disease, peripheral vascular disease, hypertension, diabetes, cancer, major depressive disorder, dysthymic disorder, anxiety, and tobacco dependence||Large sample size||Limited diagnostic accuracy and number of deaths during follow-up|
|Li et al.4||Community-based population (57,417)||10||Single RLS item question||Women: Total mortality 1.15 (0.98–1.34) Cardiovascular mortality 1.43 (1.02–2.00)||Age, race, smoking status, BMI, physical activity, alcohol consumption, sleep duration, and snoring frequency; history of major chronic diseases (arthritis, diabetes mellitus, hypertension, hypercholesterolemia, Parkinson’s disease, and use of vitamin supplements, aspirin, antidepressant drugs, and antihypertensives)||Large sample size and follow-up||Selection bias (exclusion of not ever diagnosed with RLS by physicians, recall bias), and lack of renal and neuropathy information|
Significant heterogeneity between studies was present and confirmed with the Cochran’s Q test (p = 0.0003). According to the random-effects model including the 13 selected cohort studies, the pooled HR for mortality in patients with RLS compared to non-RLS was HR = 1.52 (95% CI 1.28–1.80) (Figure 2A). Three subgroup analyses were subsequently conducted. The first subgroup analysis included only studies using the IRLSSG diagnostic criteria (n = 5).30 Among this subset of studies, heterogeneity was present (Cochran’s Q test, p = 0.001), and the pooled HR of mortality favored the association between RLS and mortality, however not reaching statistical significance (HR = 1.63, 95% CI 0.94–2.81) (Figure 2B). The second subgroup analysis included end-stage renal disease-based studies (n = 7). Heterogeneity was also present (Cochran’s Q test, p = 0.004), and the pooled HR confirmed a statistically significant association between RLS and mortality: HR = 1.41, 95% CI 1.05–1.87 (Figure 2C). The third subgroup analysis included community-based studies. However, in this case, heterogeneity was not present (Cochran’s Q test, p = 0.45), and the pooled HR confirmed the association between RLS and mortality: HR = 1.80, 95% CI 1.65–1.97 (Figure 2D). Visual inspection of the funnel plots (Figures 3A, 3B, 3C, and 3D) and Egger graphs (Figures 4A, 4B, 4C, and 4D) showed no evidence of significant publication bias regarding both the total group and subgroup analysis (Begg’s test, p = 0.07, 0.08, 0.13, 0.10; Egger’s test, p = 0.35, 0.32, 0.30, 0.21, respectively).
The real factors that determine survival in RLS are not well established, and confounding factors might influence the true relationship between RLS and mortality. Previous cohort studies are conditioned by several factors, such as a limited number of patients, the characteristics of the study population (either from the general population or belonging to end-stage renal subsets of patients), and the relatively short follow-up duration, resulting in rather few observed deaths. In this meta-analysis including 13 cohort studies, using different RLS diagnostic criteria, we observed a higher risk of mortality among patients presenting RLS, likely associated with cardiovascular diseases and especially in women, compared to non-RLS population. In contrast, mortality was not significantly different when the meta-analysis was restricted to RLS studies that used the IRLSSG diagnostic criteria.30 A thorough review of the literature provides relevant information about the factors affecting this relationship.
Although the results of the cohort studies included in this review were controlled for several known risk factors, these observational studies were not primarily designed to confirm causality. To assess the presence of RLS, earlier studies used mailed self-reporting questionnaires, a well-known and relatively inexpensive diagnostic screening method that is limited by diagnostic accuracy.7 In fact, one study showed that the four main criteria for the diagnosis of RLS applied to the general population, and not undergoing adequate differential diagnosis, wrongly classify 16% of healthy participants as having RLS.42 Similarly, the diagnostic accuracy of ICD-9 RLS codes is yet unknown.
Interview-based diagnosis using accepted international RLS diagnostic criteria30,43 is key to provide standardized RLS assessment across populations. Some years ago, the members of the Movement Disorder Society Committee on Rating Scales published a review article about the diagnostic instruments for RLS and provided recommendations based on the available evidence at that time.44 In this regard, an RLS survival study4 used a single question, included in the original diagnostic criteria for RLS, that was primarily developed for rapid screening of patients in a clinical setting.44,45 Based on its excellent sensitivity (100%) and specificity (96.8%),45 this single question may be considered a preliminary reliable screener for the diagnosis of RLS, needing subsequent confirmation by routine clinical interview.44 To improve the diagnostic accuracy, other studies33,34 have included the RLS diagnostic index with 10 items, which was developed to test the possibility that ancillary non-essential features may help to perform a more accurate diagnosis within the clinical setting, with a sensitivity of 93% and a specificity of 98.9%.46 Other diagnostic tests, recommended for clinical use (Cambridge Hopkins diagnostic questionnaire),30 and also for the general population (Hening Telephone Diagnostic Interview),47 exhibit excellent diagnostic attributes, although they have not been used in RLS survival studies.
Selection bias, like increased mortality found only in women, may be attributed to the fact that overall mortality in men generally exceeds that of women, and any factor influencing mortality in men needs to be more pronounced.40 On the contrary, as RLS is a commonly underdiagnosed condition,48 there is a tendency to include more severely affected patients, which might overestimate the true effect of RLS on global mortality. Moreover, the exact cause of death and the follow-up duration are not always clearly reported.
Regarding statistical methodology, the results of a multivariate Cox regression and propensity score method analysis can only account for the effects of known confounders. Therefore, there is a need for well-designed mortality studies analyzing age–sex standardized mortality ratios (SMR),49 in which observed deaths within RLS cohorts compared to expected deaths in the general population are reported.
Due to the heterogeneity present among studies, we conducted several subgroup analyses. Among end-stage renal and community-based populations, RLS was associated with a significantly increased mortality. According to some studies, the association between RLS and mortality seems to be influenced by advanced age, the presence of cardiovascular risk factors, end-stage renal disease, and other sleep-related conditions. However, the results provided by studies based on end-stage renal disease subjects may not be comparable to other relatively healthier populations. In community-based mortality studies, the mechanisms affecting survival in the RLS subpopulation are not well understood. Maintenance of the normal rest/activity circadian rhythm appears to be of particular importance for the preservation of general health.50 Accordingly, an increased risk of total mortality and coronary artery disease mortality has been found in RLS men presenting insomnia.38,40 Possible mechanisms linking insomnia and impaired global health include activation of inflammatory cytokines such as serum C-reactive,51 and changes of circulating levels of leptin and ghrelin proteins, which promote the development of obesity, diabetes, and cardiovascular disease.52,53 RLS patients exhibit dopamine disturbances that correlate with decreased function of the A11 diencephalospinal pathway, resulting in disinhibition of somatosensory and sympathetic pathways of the spinal cord. This may lead to an increased sympathetic activation, causing hypertension, cardiovascular disease, and stroke.6,51 Other studies relate the presence of periodic limb movements of sleep in RLS with nocturnal hypertension without a dipping pattern, which strongly correlates with left ventricular hypertrophy.54,55
In this review, we followed the PRISMA guidelines,26 applied to the search strategy, and used a well-validated meta-analytic methodology. Although cohort studies showed differences in their sampling procedures, sample characteristics, and adjustment for confounding factors, no significant publication bias was found, allowing comparability between studies. However, several limitations have to be considered when interpreting our results, including the lack of well-defined diagnostic criteria of RLS in some studies, the inclusion of mixed primary and secondary RLS studies, the possibility of having included patients with conditions mimicking RLS like diabetic neuropathy, and the small number of studies included in the subgroup analyses, which limit the extrapolation of our findings.
RLS is currently an under-recognized condition, especially by primary care physicians. The association between RLS and increased mortality has potential impact on population global health. Currently, there is a need for well-designed mortality studies addressing the SMR and the influence of any RLS-specific therapy on mortality and comorbidity. The results of this review suggest an association between RLS and increased mortality, although the existence of this association depends on the diagnostic criteria of the studies included in the analysis. Increasing awareness of RLS and future long-term follow-up standardized mortality studies is needed to confirm these findings.
1 Citation: Cubo E, Gallego-Nieto C, Elizari-Roncal M, Barroso-Pérez T, Collazo C, Calvo S, et al. Is restless legs syndrome associated with an increased risk of mortality? A meta-analysis of cohort studies. Tremor Other Hyperkinet Mov. 2019; 9. doi: 10.7916/tohm.v0.650
2 Editor: Elan D. Louis, Yale University, USA
3 Funding: None.
4 Financial Disclosures: This work was supported by a grant from the Castilla y Leon Health Department (GRS 1764/A/18).
5 Conflicts of Interest: The authors report no conflicts of interest.
6 Ethics Statement: Not applicable for this category of article.
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