A reduction in salt intake has been identified as one of the most cost-effective measures for improving health outcomes1,2,3. Different studies have reported the benefit of salt-reduction interventions in decreasing blood pressure and cardiovascular events4,5,6. Results from a meta-analysis show that modest reductions in salt intake are followed by a decrease in blood pressure levels among both hypertensive and normotensive subjects7. Nevertheless, the evidence of the effectiveness of population-level, behavior change interventions on reducing salt intake is inconsistent, suggesting that education and awareness-raising interventions alone are not sufficient for reducing population salt intake8.

Salt substitutes, that is, salt enriched with potassium or other similar components such as magnesium or aluminum, have been reported to be effective in reducing both systolic blood pressure (SBP) and diastolic blood pressure (DBP)9,10,11. Under controlled conditions, salt-substitution strategies can reduce the SBP up to 5 mm Hg and the DBP up to 1.5 mm Hg, and this effect was larger among individuals with hypertension than among normotensive subjects12. There is limited evidence, however, from studying the population-level effect of these salt-substitution interventions. A cluster randomized trial conducted in China, evaluating the effect of a community-based sodium reduction program using a salt substitute on salt consumption and blood pressure, found reductions in urinary sodium excretion but not in blood pressure13.

Currently, an increasing number of countries have adopted national salt-reduction strategies14. Salt-substitution initiatives could aid such strategies in settings where added salt during cooking is the main source of salt intake, particularly in low- and middle-income countries where hypertension rates are increasing at a fast rate15. The aim of the present study was to assess the efficacy of a pragmatic intervention using a salt-substitution strategy to reduce blood pressure, as well as its impact on the incidence of hypertension, at the population level, using a stepped-wedge cluster trial in Peru.


Population characteristics

Figure 1 shows the details of participants’ enrollment, including dates, number of subjects assessed, those lost to follow-up and those analyzed for each step of the trial. A total of 2,376 (91.2%) out of 2,605 eligible subjects in the 6 villages were enrolled in the study from 2 April to 17 July, 2014: 49.6% females, mean age 43.3 ± 17.2 years.

Fig. 1: Flowchart of participants in the stepped-wedge trial.
figure 1

LTFU, lost to follow-up. Randomization of villages occurred after baseline assessment.

Of note, only 18.9% of the individuals had ≥12 years of education, 68.1% were in the overweight or obesity range with a body mass index (BMI) ≥25 kg m−2 and 18.3% had a diagnosis of hypertension. Table 1 shows the characteristics of the study population at baseline and a comparison between the control and the intervention periods. There were differences among villages in the distribution of age, education, wealth index, BMI, SBP, DBP and hypertension (see Supplementary Table 1).

Table 1 Description of the study population at baseline by control and intervention periods

Effect of the salt substitute on blood pressure levels

In the intent-to-treat analysis, adjusting only for clustering and time effects, there was an average reduction of 1.23 mm Hg (95% CI (0.38, 2.07); P = 0.004) in SBP and 0.72 mm Hg (95% CI (0.10, 1.34); P = 0.022) in DBP among the participants who received the salt substitute compared with controls. These results remained consistent after further adjustment for sex, age, years of education, wealth index and BMI measured at baseline (Table 2).

Table 2 Overall effect of the intervention on blood pressure levels

Variations in SBP and DBP mean levels over the intervention and control periods are shown in Fig. 2. There was no evidence that the effect of the intervention was modified over time (P = 0.14 for SBP and 0.46 for DBP). Mean levels of SBP and DBP by village and intervention period are available in the supplementary files (see Extended Data Figs. 1 and 2, respectively).

Fig. 2: Trends in mean SBP and DBP.
figure 2

a,b, Trends in mean SBP (a) and DBP (b) and their respective 95% CIs by intervention or control group. Time periods are 5-month analysis periods occurring before the initiation of the intervention in each wave (n = 2,072).

Fig. 3: Structure and time framework of the stepped-wedge, cluster, randomized controlled trial.
figure 3

The assessment of participants included a short questionnaire, and weight and blood pressure measurements.

Results from exploratory analyses, shown in Table 3, showed no evidence of an interaction effect by subgroup. When the analysis was stratified by hypertension status at baseline, an average reduction in SBP of 1.92 mm Hg (95% CI (0.54, 3.29)) and 1.18 mm Hg (95% CI (0.08, 2.29)) in DBP among individuals with hypertension at baseline was observed. Among individuals without hypertension, the corresponding average reductions in SBP and DBP were 1.15 mm Hg (95% CI (0.34, 1.96)) and 0.63 mm Hg (95% CI (−0.01, 1.28)), respectively. In addition, participants did not report medication changes for the duration of the study (10.5% at baseline versus 10.1% at the end of the study (P = 0.73)). In terms of age subgroups, the effect on blood pressure among those aged ≥60 years was a reduction of 2.17 mm Hg (95% CI (0.68, 3.67)) in SBP and 1.18 mm Hg (95% CI (0.22, 2.14)) in DBP (Table 3). As a sensitivity analysis, we evaluated a possible interaction between duration of exposure and intervention effect, and did not find evidence of delayed effects (see Supplementary Table 2).

Table 3 Effect of the salt substitute on blood pressure according to hypertension status at baseline and age group (subgroup analysis)

Effect of salt-substitution intervention on the incidence of hypertension

After excluding patients with hypertension at baseline (n = 428), the data for 1,891 of the 1,914 subjects were available for analysis with 4,673.4 person-years of follow-up. The overall incidence of hypertension was estimated as 5.1 per 100 person-years (95% CI (4.5, 5.8)). In the time- and cluster-adjusted model, the participants were 51% less likely (hazard ratio (HR) = 0.49, 95% CI (0.34, 0.71), P < 0.001) to develop hypertension in the intervention period than in the control period (see Extended Data Fig. 3 and Supplementary Table 3). The Schoenfeld residual test for non-proportional hazards was not significant (P = 0.40). The observed effect of the intervention remained consistent after further adjustment for sex, age, education, wealth index and BMI (HR = 0.45; 95% CI (0.31, 0.66), P < 0.001).

Effect of salt-substitution intervention on urinary sodium and potassium

The levels of sodium in 24-h urine samples (see Supplementary Table 4) at the end of the study and baseline were 3.95 ± 1.83 (s.d.) g and 3.94 ± 1.86 g, respectively, and mean difference 0.01 (95% CI (0.25, −0.23)). These results were similar across all the study villages. In contrast, the levels of potassium were higher at the end of the study (2.60 ± 1.20 g) than at baseline (1.97 ± 1.20 g), and mean difference 0.63 (95% CI (0.78, 0.47)).


No severe adverse effects were reported for the duration of the study.


Evidence has been inconclusive regarding the efficacy of population-wide salt-reduction interventions on blood pressure. In the present study, we report the findings of a pragmatic strategy to reduce blood pressure and hypertension incidence at the population level. Overall, there was a decrease in SBP and DBP after the intervention in the entire population, with results suggesting a larger effect among those individuals with hypertension at baseline and older participants. In addition to the effect on blood pressure levels, the risk of incidence of hypertension was halved among those who received the intervention. These findings are supported by the analysis of urine samples, at baseline and follow-up, which showed an increase in mean potassium levels but no changes in sodium levels, indicating that the salt-substitution intervention was accepted and adopted. We did not find evidence of a delayed effect, suggesting that the effect is sustainable, independently of the duration of the intervention, given the nature of the stepped-wedge design.

The absolute reductions in blood pressure may appear modest, yet they carry major implications. The Prospective Studies Collaboration conducted a meta-analysis of 61 observational studies of blood pressure and vascular disease in adults and found that, for each 2 mm Hg decrease in SBP, stroke mortality and cardiovascular mortality decreased by 10% and 7%, respectively, an effect that was observed in reductions of SBP levels up to 115 mm Hg16. This indicates that small reductions in blood pressure at the population level could result in large public health gains, in line with the approaches to shift the entire distribution of a given risk factor17. The main challenge until now, however, has been how best to introduce and achieve these changes under real-life conditions. The present study demonstrates that such benefits can be introduced at a population-wide level.

Salt substitutes have been previously tested, mostly in China and mainly on patients with established hypertension12, and they show reductions in blood pressure, with a larger effect observed among individuals with hypertension. Similar results have been obtained using home blood pressure measurements18. The present study further expands the current literature by using a pragmatic population-wide intervention that included a heterogeneous sample; that is, the intervention was delivered to the general population irrespective of hypertension status (participants were or were not aware of the diagnosis), and perhaps, due to this, the effect was modest (that is, a differential effect of salt substitute in subjects with hypertension diagnosis compared with those with a recent diagnosis and those without the diagnosis). These features account for the potential scalability of our results to large populations and their influence on public health policies. The present study introduced a salt substitute containing NaCl (75%) and KCl (25%)19; however, previous reports have also included other minerals (for example, MgSO4)12,18. Potassium has also been shown to have benefits for blood pressure, irrespective of the lowering of sodium20,21,22, especially among individuals with hypertension and a high consumption of sodium23. Hence, the potassium contained in the salt substitute could contribute to the explanation of the benefits observed in the present study. This hypothesis is further supported by the higher levels of potassium, but not sodium, excretion in the urine samples at the end of the study. A higher intake of potassium could be achieved through a combined strategy of a salt-substitution intervention and health education programs that focus on promoting the consumption of fresh vegetables and fruit to increase potassium intake.

Our results also point to a lower incidence of hypertension in the participants receiving the intervention, a key clinical and public health finding. Whether this is a short-term effect (that is, the intervention did not prevent hypertension onset but rather delayed it) remains to be studied further. Because the endocrine system in charge of salt regulation, the renin–angiotensin–aldosterone system, continues to receive larger amounts of sodium or lower amounts of potassium, it is probable that blood pressure will start to increase until it reaches hypertensive thresholds24. Longer follow-ups, with and without intervention, are required to assess whether the endocrine system develops salt resistance. However, our findings show no evidence of an interaction between time and intervention.

From the viewpoint of pragmatic implementation, we provide evidence for the ability to introduce a salt substitute to entire participating communities after a social marketing campaign designed to improve its acceptance. With evidence that antihypertensive medication is often unavailable or unaffordable in many low- and middle-income settings25, the implementation of a similar primary prevention strategy could reduce the burden associated with hypertension and its cardiovascular complications. The cost of the salt substitute should also be considered. During the present study, before the intervention the cost of 1 kg of the salt substitute to the general public was 35 PEN (~$US10), and through the project we were able to achieve a price reduction to 14 PEN (~$US4), further indicating opportunities for scaling up implementation efforts.

Current hypertension guidelines advocate non-pharmacologic treatment, even in patients with low-risk, stage 1 hypertension26. Our results provide evidence of a pragmatic approach that reduces blood pressure and, secondarily, halves the incidence of hypertension. These guidelines have also lowered the threshold for hypertension, meaning that more people will receive this diagnosis and need to incorporate essential hypertension management strategies, making it difficult for health systems to provide pharmacologic treatment and counseling to new patients. Moreover, given the alarming rates of non-adherence to medication for hypertension globally, non-pharmacologic measures to improve blood pressure control at the population level are urgently needed. This population-wide intervention has the potential to contribute to reducing overall blood pressure levels without additional overcrowding of the healthcare system, potentially saving healthcare costs27.

In Peru, and in many other resource-constrained settings, there are different venues through which a salt substitute can be introduced to replace the current salt, including, for example, community kitchens for people of low socioeconomic status28, a different national program for providing nutritious breakfasts for children attending public schools in rural areas or elderly people. Therefore, the logistics underlying this process are already in place and could be adapted to provide patients with hypertension, and their families, with a salt substitute. Similar scenarios may be present in other countries, signaling a window of opportunity to introduce a seemingly effective tool to reduce blood pressure. Other countries, including high-income countries, could also accommodate a similar salt-substitution approach using existing channels and various venues, including school feeding programs.

The present study is an intervention study that provides a high level of evidence. The randomized allocation of the intervention removes several biases that exist in non-randomized studies, even after adjusting for potential confounders. The stepped-wedge design guarantees a pragmatic scheme in which randomization of the intervention is protected, allowing a large population to be reached. In some villages a reduction in blood pressure was observed before the intervention, and potential explanations for this could be a community-like white coat effect, which, in the case of rural or semi-urban areas with limited access to healthcare, can also be present. Another explanation could be regression to the mean. In both circumstances, the repeated measurements would be the best way to overcome such potential weaknesses. The repeated follow-up visits over short, equally spaced periods, a characteristic of the stepped-wedge design, augmented the statistical power and afforded additional strength to address regression to the mean. In addition, uptake of the intervention was objectively assessed, with urine samples demonstrating more potassium excretion at the end of the intervention, suggesting that the intervention was indeed well received and the salt substitute used. Consistently, the intervention included a social marketing campaign to guarantee adoption of the new salt. From a public health perspective, the delivery of the intervention at the population level following a pragmatic methodology could inform prevention guidelines and policies to control the rising burden of increased blood pressure worldwide. Nevertheless, the limitations of the study must also be acknowledged. First, the absence of a dietary assessment of other sources of sodium and potassium could have an impact on our results; however, this factor should be negligible because of the population-wide approach used. We provided whole villages with the salt substitute, also targeting families who prepare and sell food as street vendors. Therefore, it seems unlikely that other sources of sodium could have contaminated the intervention. Similarly, it is also unlikely that other sources of potassium confounded the intervention. To prevent any potential harm, and thus protect the safety of the study population, we did not include people with kidney disease or those receiving digoxin (used as a proxy of cardiovascular disease). Although this exclusion warrants close follow-up of these patients, including regular check-ups with their physicians or tailored diets, it does not affect the implementation of wider population-wide benefits aimed at lowering blood pressure. Finally, despite the inclusion of urine data from individuals with a complete 24-h urine sample, the levels of creatinine appear to be somewhat lower at baseline than during follow-up, thus reflecting some under-collection at the beginning of the study. However, we believe that this may have a negligible effect, because the creatinine levels were in the normal range. Moreover, the variation observed in the levels of creatinine was within the range of dispersion (SD) of measurements.

Our results provide evidence that a population-based intervention to replace regular salt with a low-sodium, potassium-enriched salt reduces both SBP and DBP, particularly in people with hypertension. In addition, the intervention halved the incidence of hypertension. This pragmatic intervention could be adapted and scaled up to counter the high burden of elevated blood pressure currently observed worldwide.


The study protocol and methods have been described previously29, and a summary is provided below. The CONSORT statement for randomized cluster trials30 and recent literature on reporting results of stepped-wedge cluster trials31,32 were utilized.

Study design

A stepped-wedge, cluster, randomized controlled trial was conducted, in which the six participating villages (clusters) crossed over from the control to the intervention phase during the study33. The order of switchover for each cluster was determined by randomization, and all villages received the salt substitute by the end of the study. The structure of the stepped wedge is provided in Fig. 3, where the intervention periods (village implementation phases, shown in gray) lasted 4 months, and blood pressure measurements were made every 5 months after the baseline period. The study was undertaken between April 2014 (start of baseline assessment) and March 2017 (last measurement and assessment).

Study setting

Tumbes, a coastal region in northern Peru, bordering Ecuador, was the setting selected for the present study because hypertension prevalence and incidence rates are above the national average34,35. According to official estimates of the Tumbes population36, in 2017 there were 243,362 inhabitants with a life expectancy of 75 years; 20% of the population did not have any health insurance and 12% were below the poverty line. The semi-urban area of the region, with approximately 100 villages of varying sizes and approximately 80,000 inhabitants, was the area chosen for the study. Mid-sized villages with 350–700 individuals (~130–250 households) were initially selected for the study. Of the 20 villages available with these characteristics, 6 were randomly selected. Sufficient distance between them was also ensured (that is, a median of 14 km (interquartile range 7.1–17.1) between them) to avoid contamination by verifying the selection of villages on the map.

Participants and recruitment

Potentially eligible subjects were identified from the most updated census in the area (2010, updated in 2014). All men and women aged ≥18 years from the six selected villages, who were capable of understanding procedures and of providing informed consent, and full-time residents in the area, were eligible. Individuals with a self-reported history of chronic kidney disease or of heart disease treated with digoxin were excluded from the study.

Participant recruitment, as well as the initial assessment, was performed during the first 4 months of the study (April to July 2014). Individuals were contacted through home visits aiming to enroll all members of households in the villages who met the selection criteria.

Randomization and blinding

The selected villages were randomly assigned to one of the six sequences (one village = one cluster) for time crossover from control to intervention. For this, a computer-generated list of random numbers was used and information was kept in a password-protected computer. The order of the villages to be implemented was revealed one by one as required, according to the nature of the study. Due to the pragmatic nature of the intervention, the participants were not blinded; however, the primary study outcome was objectively measured using standardized techniques. A team of fieldworkers, not involved with the implementation of the intervention, was responsible for periodic assessments of participants using automated devices to reduce observer bias.


Through the application of social marketing strategies37, a campaign was developed to target women responsible for food preparation at home. The purpose of the marketing campaign was to introduce the salt substitute as a new product in the intervention villages, and enhance its acceptance. Thus, common salt (NaCl) used in the enrolled households was retrieved and replaced, free of charge, with a salt substitute, using a combination of 75% NaCl and 25% KCl, based on previous research19. Iodine, in addition to fluorine, was also part of the salt substitute following Peruvian regulations38. As the usual cost of a bag of 1 kg of common salt in the region was between $US0.15 and $US0.17 (about 0.50 PEN), we provided the salt substitute free of charge to the participants in their respective homes.

The time for provision of a salt replacement was planned to happen over a period of 5 months in each village; however, there was a delay in salt-substitute delivery of, on average, 15 d. The intervention considered making the salt delivery to families, as well as to owners of small shops, bakeries and community kitchens28, and food vendors including street vendors and restaurants. This approach was used to guarantee full replacement of salt in the entire village. Additional salt-substitute packs were also made freely available during the study period in case any household required additional salt.

Outcomes and data collection

The primary outcomes were SBP and DBP, assessed as continuous variables (in mm Hg) evaluated in the period between the end of each wedge and the start of the next one. Blood pressure assessments were performed with the participants seated, after a 5-min resting period, using an automated device (OMRON HEM-780) that had been previously validated in adult populations39. Three different measurements, at least 1 min apart, were carried out, and the average of the second and third measurements was used for the analyses.

The secondary outcomes included progression toward hypertension (incidence) and, in a random subsample of participants, changes in levels of sodium and potassium excretion in the 24-h urine. Hypertension at baseline was defined as SBP ≥ 140 mm Hg, DBP ≥ 90 mm Hg, a self-reported physician diagnosis or current treatment for hypertension40. During follow-up, hypertension was defined in two ways: considering only the study measurements (average of the second and third measurements, with the participant in seated position, after resting 5 min, and at least 1 min between measurements) or taking advantage of the repeated assessments conducted every 5 months, as well as using the same definition as in the baseline.

After providing consent, each participant was given a unique code. At baseline, detailed information about sociodemographics (for example, age, sex, education and wealth index), lifestyle behaviors (smoking, alcohol consumption and physical activity), self-reported personal medical history and medication (hypertension and type 2 diabetes mellitus), anthropometric measurements (height, weight and blood pressure), and healthcare utilization and expenditure was collected using paper-based formats. Follow-up assessments were conducted in all participants and included some lifestyle behaviors (smoking and alcohol consumption), anthropometric measurements (weight and blood pressure), and healthcare utilization and expenditure.

Urine samples were retrieved in a random subsample of 600 participants after baseline and in another randomly selected subsample of 600 participants at the end of the study. Only one participant per household was included in the urine assessments. Urine samples were collected over a 24-h period, and all samples were assessed in a central laboratory facility. These samples were used to extract information about levels of creatinine, sodium and potassium. Sodium and potassium were assessed using the ion-selective electrode method, whereas creatinine was assessed using the compensated kinetic Jaffe method.

Statistical methods

All statistical procedures were conducted using Stata for Windows v.15.0 (StataCorp) and R statistical software41, and a per-protocol, intent-to-treat analysis was performed. A pre-specified linear mixed effects regression analysis was performed to model SBP and DBP using an identity link, an unstructured working correlation, including covariates for intervention status and time period, which was considered as a factor, and random effects for village, family and repeated observations of the same individual over time42,43, and robust variances were computed. Thus, the following model was used:

$$Y_{ijkl} = \mu + \alpha _i + \gamma _j + \varphi _k + \beta _l + \theta X_{kl} + \varepsilon _{ijkl}$$

where Yijkl is the SBP (or DBP) measured for individual i, in family j, at cluster k, in time l; μ is the mean outcome in the control group at baseline; αi is a random intercept of individual i; γj is a random intercept for family j; φk is a random intercept for cluster k; β is the effect of time l; Xkl is an indicator of the treatment mode in village k at time l; θ is the overall effect of the intervention; and εijkl is the random error for the measurement of individual i, in family j, at cluster k, at time l.

We also evaluated, as a sensitivity analysis, whether there was evidence of a delayed effect, that is, an interaction between duration of exposure and intervention42, and estimated the effect of the intervention on SBP and DBP, controlling for assumed defined possible confounders: age, sex, education, wealth index and BMI at baseline. Furthermore, we conducted exploratory subgroup analyses by hypertension status and age group defined at baseline.

For incidence calculations, Cox’s proportional hazard modeling on a calendar time axis, to account for time trends with random effects that follow gamma distribution for village-level (shared) frailty, was considered to compare the instantaneous risk of hypertension for both the intervention and the control groups44. The Schoenfeld residuals were used to test for the non-proportional hazard without considering the frailty term45. Time- and cluster-adjusted Cox’s models were constructed for the primary analysis, and fully adjusted models were generated to account for confounding variables such as age, sex, education, wealth index and BMI at baseline. Calculations (that is, HRs) were estimated taking into account the clustering of villages; in addition, a time-varying binary covariate tracking intervention status was fit, using definitions of times at risk in each of the periods described above.

Finally, changes in the 24-h urine concentrations of sodium and potassium were also evaluated (at the end of the study and after baseline). For the analysis, we included only individuals with a complete 24-h urine sample, defined as (1) at least 500 ml and (2) creatinine <4 mmol dl−1 in women or <6 mmol dl−1 in men46,47. Comparisons were conducted using the Student’s t-test for independent samples.


This project was registered in (no. NCT01960972). The protocol and informed consent forms used in this project were reviewed and approved by the institutional review boards of Universidad Peruana Cayetano Heredia, Lima, Peru, and Johns Hopkins University, Baltimore, MD, USA. Given that the intervention was implemented at the village level, but the outcome was measured at the individual level, we involved all the members of the recruited families in the study. For this, we initially engaged with the authorities and leaders from the villages, and an initial presentation and explanation of the study at the village level were conducted before starting the research activities. Then, family members aged ≥18 years were contacted for individual informed consent. As hypertension is not common among children, we did not include children and adolescents, that is any family member aged <18 years, in the study. Participants with a history of terminal or severe chronic kidney disease (any form of dialysis) or those taking digoxin or potassium-sparing diuretics (for heart disease), together with their families, were excluded from this study.

Reporting summary

Further information on research design is available in the Nature Research Reporting Summary linked to this article.