Background

Strongyloides stercoralis and hookworms are parasitic intestinal nematodes that belong to the group of soil-transmitted helminths (STH). For both parasites, infection occurs when larvae living in faecally-polluted soil penetrate intact skin. STH mostly affect the poorest, locking them into poverty through a cycle of gastro-intestinal symptoms, malnutrition and long-term impact on fitness and productivity [1,2,3]. With overlapping geographical distributions, STH are mostly prevalent in rural areas with poor sanitation conditions and a warm and humid climate that favour larvae survival in the environment [2, 4, 5].

Hookworm infection is of major public health importance in low and middle-income countries, with 439 million cases reported worldwide in 2010 [6]. Hookworm causes the highest burden among STH, with detrimental effects on children’s physical and cognitive development and agricultural workers’ productivity. It also gives rise to hookworm disease, which occurs in cases of high worm load and causes iron-deficiency anaemia that affects infant and maternal mortality and leads to low birth weights [2, 3, 7, 8].

As for S. stercoralis, it is one of the most neglected of the neglected tropical diseases (NTDs), mostly because its larvae, present in human stool, are not detected by the diagnostic coprological techniques used in endemic countries to screen for helminth eggs [5, 9,10,11]. However, the parasite has recently gained some attention from the scientific and global health community and recent studies in Cambodia found high prevalence rates of up to 45% [12,13,14]. Not only is this parasite very common, but it also causes significant dermatological and gastro-intestinal morbidity and is associated with chronic malnutrition in children [15, 16]. Moreover, its ability to replicate within its host leads to long-lasting infections and potentially fatal dissemination of the parasite [17,18,19].

The backbone of the WHO strategy to control STH is preventive chemotherapy (PC), i.e. regular treatment to prevent high-intensity infections and associated morbidity administered to entire populations or at-risk groups. In the case of hookworm, children and women of childbearing age are particular targets for treatment [20, 21]. However, continued exposure to contaminated environments due to unhygienic behaviour leads quickly to re-infection [22,23,24] and re-treatment is required.

To date, S. stercoralis is not included in the WHO recommended preventive chemotherapy control strategy used against STH, in which anti-helminthic treatment is the main pillar. The drug of choice against S. stercoralis, ivermectin, is safe, well tolerated and highly efficacious [25,26,27]. It was recently found that a single oral dose (200 μg/kg body weight (BW)) of ivermectin achieved a high cure rate and resulted in re-infection rates below 15%, one year after treatment in a highly endemic setting in Cambodia [24,25,26].

Both S. stercoralis and hookworm are highly prevalent in Preah Vihear Province [28, 29]. Considering the need to integrate S. stercoralis control into existing STH programmes, it is important to know the extent to which the distributions of the two parasites overlap geographically and across age groups. Geostatistical models using survey parasitological data combined with remote sensing (RS) environmental data provide unique tools for estimating parasite distribution over small or large areas, thereby providing a rapid and cost-effective means of identifying the areas of greatest need and guiding control efforts [30,31,32].

The aim of the present work was to assess the geographical distribution and explore the underlying factors of S. stercoralis-hookworm co-infection risk in the rural Province of Preah Vihear, northern Cambodia.

Methods

Study setting and design

The study was conducted among the general population of Preah Vihear Province, located in northern Cambodia and bordering Thailand. With a population of 171,139 in 2008 and a total area of 16,132 km2, the province stretches from 13°06′ to 14°44’N, 104°37′ to 106°91′E [33]. The poverty incidence, defined as the proportion of individuals living in households with an average per capita expenditure below the poverty line of 6347 riels (1.55 USD), was 33.5% in 2009 [34]. It has a monsoon type climate, with a rainy season occurring from May to October. Strongyloides stercoralis and hookworms, as well as protozoa, are highly endemic in this region [12].

Sixty of the 184 villages in Preah Vihear province were selected for a large-scale, cross-sectional study carried out from February to June 2010. Six of seven districts were included; the district of Chaeb was excluded because the distance between its villages and the study laboratories was too large to ensure sufficiently fast transfer of samples to preserve their integrity. In each village, 15 households were randomly selected from the list of all households and all household members aged one and over were eligible for inclusion in the study.

Parasitological data and case definition

Two stool samples were collected on consecutive days from each participant. Strongyloides stercoralis was diagnosed using both Koga agar plate (KAP) culture and the Baermann technique performed on each sample [35, 36]. A detailed description of this laboratory procedure is given elsewhere [12]. Hookworm was diagnosed using Kato-Katz thick smears, KAP culture and the Baermann technique on each sample. Strongyloides stercoralis larvae and hookworm eggs were identified through microscope examination and based on morphology. For quality control, technicians were specifically trained to differentiate S. stercoralis and hookworm larvae. In addition, they were rigorously supervised by a qualified microscopist from the Swiss Tropical and Public Health Institute (Swiss TPH), Basel, Switzerland. Any unclear diagnosis was immediately discussed with both the qualified microscopist and the study supervisor.

In this analysis, infection status was defined as follows. For S. stercoralis, a participant was considered positive if at least one larva was found in any of the four samples (KAP and Baermann technique on two samples) or negative if no larva was detected in the four samples. Participants with only negative results but with fewer than four analysed samples were not included in the analysis. For hookworm, a participant was considered positive if at least one egg was found in any of the six samples (Kato-Katz, KAP, and Baermann technique on two samples), and negative if both Kato-Katz slides were negative. Negative participants with one missing Kato-Katz examination were not included in the analysis. All reported results in this paper use the definitions described above.

Demographic, socioeconomic, knowledge and hygiene practices data

Data on demographic factors (age, sex, main occupation, level of education), hygiene practices (hand washing, shoe wearing, regular place of defecation), and worm-related knowledge (sources of infection, health problems caused by worms) were collected with an individual questionnaire. Heads of households were administered an additional questionnaire to collect information on household size, water and sanitation conditions, house material and household asset ownership. Age was categorized into four classes, as follows: (i) < 6 years; (ii) 6–18 years; (iii) 19–49 years; and (iv) ≥ 50 years. About 17% (432/2576) of the participants reported their occupation as “other”, most of whom declared being at home (361/432), while the remaining occupations varied from teachers, nurses and military, to village chiefs and construction workers. Original categories of variables with frequencies under 5% were grouped with similar categories.

An asset-based socioeconomic index was built using house construction material, ownership of household assets and multiple correspondence analysis (MCA), a data reduction technique that was developed for categorical data [37, 38]. Households were classified into one of three wealth classes, from the least poor to the poorest.

Environmental data

Environmental parameters were extracted from freely available remote sensing (RS) sources. Day and night land surface temperature (LST), land use/land cover (LULC), and enhanced vegetation index (EVI) were extracted at 1 × 1 km resolution from Moderate Resolution Imaging Spectroradiometer (MODIS) Land Processes Distributed Active Archive Center (LP DAAC), U.S. Geological Survey (USGS) Earth Resources Observation and Science (EROS) Center (http://lpdaac.usgs.gov). EVI was used instead of the normalized difference vegetation index (NDVI), as it is more sensitive to differences in heavily vegetated areas and, thus, more appropriate for Southeast Asia (see http://earthobservatory.nasa.gov/Features/MeasuringVegetation/measuring_vegetation_4.php). Rainfall estimates (RFE) at 0.1 degree (about 10 × 11 km) resolution were obtained from the National Oceanic and Atmospheric Administration’s (NOAA) Climate Prediction Center (CPC) Famine Early Warning System (FEWS) Rainfall Estimates South Asia, version 2.0 (http://www.cpc.ncep.noaa.gov/products/international/). Digital elevation data at a resolution of 90 × 90 m were retrieved from the NASA Shuttle Radar Topographic Mission’s (SRTM) Consortium for Spatial Information of the Consultative Group for International Agricultural Research (CGIAR-CSI) database. Soil type data, including bulk density, soil organic carbon content and pH, at a spatial resolution of 9 × 9 km, were extracted from the International Soil Reference and Information Center’s (ISRIC) World Inventory Soil Emission Potentials (WISE), version 1.0 (http://www.isric.org). District information (i.e. district name) was downloaded from the Global Administrative Areas website (http://www.gadm.org). The 18 land cover type 1 classes (IGBP) were merged into five categories, according to similarity and respective frequencies. Yearly means, as well as minima and maxima of EVI, monthly LST and RFE were calculated for May 2009 to April 2010.

Statistical analysis

ArcGIS version 10.0 (ESRI; Redlands, CA, USA) was used for environmental data processing, geo-referencing and map drawing. Environmental data was linked to parasitological and questionnaire data according to location. Data management was performed in STATA version 13.0 (StataCorp LP; College Station, USA).

Bayesian mixed multinomial models, i.e. with a random effect accounting for village-level clustering, were used to jointly model the risks of mono-infection with S. stercoralis, mono-infection with hookworm, and S. stercoralis-hookworm co-infection. Such a model yields relative risk ratios for categorical outcomes (here, the two mono-infection and the co-infection risks) compared to a baseline outcome (in the present case, “no infection”). Two types of Bayesian mixed multinomial models were developed. First, a model using demographic, socioeconomic and behavioural data was developed to assess determinants of S. stercoralis and hookworm mono- and co-infection. Second, a model including only environmental covariates aimed to predict S. stercoralis-hookworm mono- and co-infection risks at non-surveyed locations in Preah Vihear province.

Variable selection for both types of models was done in STATA using simple multinomial models, based on 15% significance level as assessed by the likelihood ratio test (LRT). In case of correlation, the variable resulting in the model with the smallest Akaike’s information criterion (AIC) was selected. Selected continuous covariates were standardized. We checked whether sex was an effect modifier of any other variable in the model.

A mixed logistic regression model for S. stercoralis infection was used to estimate the odds ratio for co-infection with hookworm; this was done in STATA, while adjusting for all the variables present in the determinant analysis. The unadjusted odds ratio was produced using a mixed bivariate logistic regression.

Bayesian multivariate mixed multinomial models were fitted using OpenBUGS version 3.2.3 (Imperial College & Medical Research Council, London, UK) [39]. Models without or with environmental covariates were run with either a spatial (geostatistical) random effect, using the OpenBUGS “spatial.unipred” function, or with an exchangeable random effect. To explore the clustering tendency of S. stercoralis and hookworm mono- and co-infection risks, a Bayesian spatial multinomial model was run in the absence of covariates. Spatial models assumed a stationary isotropic process, with village-specific random effects following a normal distribution with mean zero and a variance-covariance matrix being an exponential function of the distance between pairs of locations. Vague prior distributions were chosen for all other parameters. Markov Chain Monte Carlo (MCMC) simulation was used to estimate model parameters [40]. Convergence was assessed by examining the ergodic averages of selected parameters. Further information about models specification is available in Additional file 1. For all models, a burn-in of 5000 was followed by 30,000 iterations, after which convergence was reached. Results were withdrawn for the last 10,000 iterations of each chain, with a thinning of 10.

For model validation, 48 randomly selected villages were used for fitting and the 12 remaining villages were used as test locations. Model predictive ability was assessed with the Mean Squared Error (MSE), which was obtained for test locations by squaring the average of absolute differences between predicted and observed prevalence rates.

Based on environmental factors only and using Bayesian kriging, predictions of S. stercoralis mono-infection, hookworm mono-infection and S. stercoralis-hookworm co-infection risks at non-surveyed locations were made at 16,532 pixels of a 1 × 1 km resolution [41].

Results

Study population and size

Of the 3560 participants with available questionnaire data, 221 did not provide any stool sample. The case definition used in the present study resulted in the further exclusion of 662 S. stercoralis negative participants with fewer than four available diagnostic tests (KAP and Baermann on two samples) and 101 hookworm negative participants with fewer than two available diagnostic examinations (Kato-Katz on 2 samples), resulting in a sample of 2576 participants. While this sample was used for the predictive model, the final sample for the determinant analysis consisted in 2502 participants (70.3%) with complete questionnaire data and covering in 769 households and 60 villages. The characteristics of those 2502 participants are presented in Table 1.

Table 1 Characteristics of participants included in the analysis
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The proportion of males and females, and those who had ever been treated for worms were similar in the groups of excluded and included participants. Children under the age of six were less represented in the analysed sample (7.7%) than in the group of excluded participants, due to missing diagnostic results (24.6%). This was also reflected in the variable “occupation”, for which participants spending their time “at home” were also less represented. This group of participants consisted mostly of children, as adults were evenly distributed in the two groups. Participants declaring regularly defecating in toilets or behind their house were less represented in the included group, as well as those declaring wearing shoes “sometimes or never”. All those variables were therefore adjusted for in the multivariate model, with the exception of occupation, which was collinear with age and thus removed from the model (see below).

Strongyloides stercoralis and hookworm prevalence

About two in three (1749/2576) participants were infected with S. stercoralis (1252 cases) or/and hookworms (1263 cases). The overall prevalence of S. stercoralis was 48.6% [95% confidence interval (CI): 46.7–50.6%], with 61.2% (95% CI: 58.4–63.9%) of S. stercoralis cases being co-infected with hookworms. The overall prevalence of hookworm was 49.0% (95% CI: 47.1–51.0%), with 60.6% (95% CI: 57.9–63.4%) being co-infected with S. stercoralis. Of the 1089 hookworm cases for which egg counts were available (i.e. 86.2% of hookworm cases with at least one positive Kato-Katz slide), most (1044/1089, 95.9%) were of light intensity according to the WHO classification [1–1999 eggs/g (epg)], whereas the remaining infections were either of moderate (2.0%) or heavy (2.1%) intensity. Individuals infected with S. stercoralis had double the odds of being infected with hookworm [unadjusted odds ratio (OR): 2.49 (95% CI: 2.10–2.97), adjusted OR: 2.21 (95% CI: 1.84–2.66)].

Determinants of S. stercoralis and hookworm mono- and co-infection risks

The results of bivariate multinomial regressions are available in Additional file 2: Table S1. Occupation and age were collinear, and occupation was removed from the model since it was not a confounder of any other variable and its removal yielded a lower AIC in the multivariate model (AIC with occupation: 6314.8, AIC without occupation: 6311.2). No interaction was found.

Table 2 presents the results of the multivariate Bayesian mixed multinomial regression, accounting for village heterogeneity and jointly assessing determinants of each parasite mono- infection or co-infection as compared to non-infected participants. Females had lower odds of any infection type. The risk of being infected with S. stercoralis peaked among participants over 50 years old, the odds of hookworm mono-infection was lower for preschool-aged (age < 6 years) children, and co-infection risk was lower among preschool-aged children and adults between 19 and 49 years old. The poorest individuals had higher odds of either mono-infection or co-infection. Toilet use was a protective factor against hookworm mono-infection or co-infection, while co-infection risk was higher among participants living at larger distances from a health centre.

Table 2 Determinants of hookworm and S. stercoralis mono- and co-infection. RRR in bold were significant at 5% level. Data were obtained from a cross-sectional survey conducted in 2010 in 60 villages of Preah Vihear Province, North Cambodia, among 2502 participants aged 1 year and older
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Clustering tendency of S. stercoralis and hookworm mono- and co-infection

Strongyloides stercoralis exhibited almost no spatial correlation as indicated by the low location-specific variance and range, even in the absence of parameters. Hookworm mono-infection and co-infection exhibited moderate clustering tendencies, both with cluster sizes of about 20 km. Parameters of the three following multinomial geostatistical models are presented in Table 3: (i) model without covariates; (ii) predictive model including only environmental factors; and (iii) determinant analysis model including district and demographic, socioeconomic and behavioural factors.

Table 3 Model parameters of three geostatistical models
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Prediction of S. stercoralis and hookworm mono- and co-infection risks

Of the three pairs (exchangeable vs geostatistical random effect) of models submitted to variable selection, model validation indicated that the geostatistical model, including LST day minimum, LST night mean, soil organic carbon, land use land cover, and RFE maximum, had the best predictive ability as assessed by the MSE. Results of the model validation are available in Additional file 3: Table S2. Relative risk ratios (RRR) of the predictive models are presented in Table 4.

Table 4 Results of the geostatistical multinomial predictive model. RRR in bold are significant at 5% level. Data were obtained from a cross-sectional survey conducted in 2010 in 60 villages of Preah Vihear province, North Cambodia, among 2576 participants aged over 1 year
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Figure 1 presents the maps of predicted S. stercoralis and hookworm mono- and co-infection risks. The two parasites, as well as co-infection cases, were ubiquitous in the province. The distributions of mono-infection with each parasite appeared complementary, with relatively higher risk of S. stercoralis and lower risk of hookworm in the North-West. The highest rates of co-infection were found in the South-West, East and North of the area. Model uncertainty for each predicted outcome, as expressed by the ratio of the posterior median over its standard deviation (error coefficient), is presented in Fig. 2. A smaller value indicates a larger degree of uncertainty.

Fig. 1
figure 1

Maps of predicted hookworm mono-infection (a), S. stercoralis mono-infection (b) and co-infection (c) risk in Preah Vihear Province, North Cambodia. Predictions correspond to the posterior median obtained with the geostatistical multinomial model described in Table 3

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Fig. 2
figure 2

Error coefficients of the predicted hookworm mono-infection (a), S. stercoralis mono-infection (b) and co-infection (c) risk in Preah Vihear Province, North Cambodia. The error coefficient is the ratio between predicted median and its standard deviation. Darker zones indicate higher uncertainty

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Discussion

This first S. stercoralis-hookworm co-risk map underlines the ubiquity of the two parasites and high prevalence rates in Preah Vihear Province, with more than two in three participants infected with one of the parasites and almost half (44%) experiencing co-infections.

In Cambodia, S. stercoralis infection was recently found to be associated with significant morbidity, and calls for control have been acknowledged [12, 42]. The hookworm situation, whereby half of the study participants experienced mostly light infections (2% both for moderate and heavy intensity classes), raises some questions. Infection levels were particularly high in school-aged children (SAC), with a prevalence rate similar to that of the late nineties, and infection intensity levels remaining above the 1% WHO control target for each intensity class [28, 29, 43,44,45,46].

STH control programmes reportedly achieve high coverage rates in Cambodia, but the assessment methods remain unclear, particularly with respect to the impact of school enrolment (net ratio was 65.2% in 2005 in Preah Vihear) [28, 29, 47]. An important aspect of programme evaluation is to estimate both coverage, i.e. the proportion of eligible population who received tablets, and compliance, i.e. the proportion of eligible population who actually swallowed tablets; these components can be substantially different, with the latter being the best measure of programme effectiveness [48].

Additionally, STH control programmes in Cambodia deliver mebendazole, which has a significantly weaker effect on hookworm infection than albendazole [49,50,51]. Decreased mebendazole efficacy against hookworm has raised concerns in Southeast Asia [51,52,53]. Reasons for its low performance should be investigated and explore both potential resistance and efficacy on Ancylostoma ceylanicum, a hookworm of dogs and cats that is highly prevalent among humans in Southeast Asia, and in Preah Vihear Province [54,55,56,57,58].

Another cause of persistent hookworm infection might be high reinfection rates, which can reach around 60% one year post-treatment for hookworm [23]. Documenting hookworm reinfection rates in the country might help disentangle the reasons why hookworm infection levels remain high [24].

Individuals living in the poorest households had higher odds of co-infection or mono-infection with any parasite, which reconfirms that STH infections, including S. stercoralis, are diseases of poverty [3, 7, 59]. The use of a robust method to construct the socioeconomic index might explain this result, since S. stercoralis was not associated with socioeconomic status in the few studies that accounted for it [13, 55]. The higher odds of infection with either parasite alone or concurrently among males were in line with results from other studies conducted in Asia [13, 55, 60,61,62,63]. School-aged children and adolescents had the highest risk of being co-infected, suggesting that this age group is an important target for control of both parasites in this setting. Treatment decreased the odds of hookworm mono-infection, but did not affect the odds of being infected with S. stercoralis, against which it is not effective at a single oral dose [49]. Defecating in toilets, boiling drinking water and having been treated with anthelmintics were protective factors against co-infection. The role of sanitation in STH transmission is widely acknowledged, whereas the association between systematically boiling drinking water and co-infection is unexpected, given the infection route of these two parasites [64,65,66,67]. This variable most likely acted as a proxy for overall hygienic health-promoting behaviour. Yet, an oral infection route has not been excluded for S. stercoralis; Ancylostoma duodenale can also infect orally, although it occurs rarely in this setting [57, 68, 69].

The spatial dependence of co-infection was mostly attributable to hookworm, as S. stercoralis exhibited almost no clustering tendency, even in the absence of covariates. This does not preclude, however, that S. stercoralis risk would cluster at a larger scale. Environmental factors partly explain the clustering of all outcomes (as indicated by the decrease in unexplained variance (σ2) and the drop of the range after inclusion of environmental variables). Climatic parameters influencing the distribution of the two parasites have been discussed elsewhere. Two previously identified factors are increased temperature and rainfall, either preventing or favouring larvae survival through desiccation or wetness, respectively [4, 12, 70]. Model parameters indicate that socio-demographic and behavioural variables played an important role in explaining the spatial variation of hookworm mono-infection and co-infection, but less so for S. stercoralis mono-infection. This result might reflect variability in mebendazole PC effectiveness across provincial regions, which cannot be excluded, despite adjusting for anthelmintic treatment. Indeed, we only adjusted for self-reported treatment, which is subject to recall bias, particularly after several deworming rounds [71]. We analysed data from 2010; since then, STH control with mebendazole has been scaled up to include additional age groups. Up-to-date studies accounting for programme coverage and compliance would help to assess the respective roles of environment, control and behaviour on infection levels with the two parasites.

Our study has some limitations. Although including only the negative participants with complete results ensured high specificity while keeping the maximum number of positive observations in the sample, it resulted in overestimated prevalence rates for both parasites, i.e. 48.6 vs 44.7% with a complete case analysis for S. stercoralis and 49.0 vs 39.6% for hookworm. Additionally, we did not address infection intensity of hookworm infection but most cases were of light intensity and geostatistical predictive models for infection intensity usually yield substantial uncertainty, particularly in low intensity settings [62, 72, 73]. Children under six years were under-represented in the sample, due to insufficient stool amounts for performing the Baermann technique, a shortcoming that will keep occurring as long as combining Baermann and KAP provides the most sensitive diagnostic approach for prevalence surveys. This aspect underlines the need for new techniques to diagnose S. stercoralis in endemic settings [74, 75]. No established prevalence thresholds exist for S. stercoralis, so we used those defined for other STH, although infection levels relating to the public health importance of this parasite might differ [10, 42]. The relationship between S. stercoralis infection intensity and morbidity, including potential co-morbidity arising from multiple infections needs to be investigated [76, 77].

There is a general agreement that S. stercoralis, now recognised as a major public health problem in Cambodia, needs to be integrated into existing STH control programmes [12, 13, 16, 24, 42, 78]. Under the present national policy, this integration would result in combining mebendazole with ivermectin, a combination found to be safe among schoolchildren in Zanzibar, but that has otherwise been rarely investigated [50, 79,80,81]. The combination of ivermectin with albendazole has largely proven to be safe for long-term use to control filarial diseases and also appears to add-value in the treatment of STH, including hookworm. [21, 46, 49, 79, 80, 82,83,84,85,86,87].

Drug combination is usually associated with a lower risk of emerging resistance, however the appearance of resistance to benzimidazoles might be accelerated by combining it with ivermectin, so any co-distribution should be closely monitored [88]. Cost-effectiveness studies of S. stercoralis control options, including the ancillary benefits of extending hookworm control coverage to adults and a potential switch to albendazole, are also needed.

The high impact that community-based, targeted ivermectin treatment achieved in Cambodia suggests that S. stercoralis control with PC is feasible. This assertion is supported by studies in several countries that documented a high ancillary impact of large-scale distribution of ivermectin against filarial diseases on S. stercoralis [42, 79, 89–91]. Still, longitudinal studies should be conducted to further confirm the impact of community-based PC with ivermectin in endemic settings of various transmission levels [24].

A major issue limiting the implementation of S. stercoralis control in Cambodia is the high cost of ivermectin, which is not donated in areas free of onchocerciasis. Ivermectin subsidization, donation, or production in the form of affordable generics are more likely once S. stercoralis is recognised as a public health problem and listed in the WHO PC strategy. A sensitive rapid diagnostic test would be crucial for efficient data collection and prevalence estimation at large scale [75].

In the meantime, the efficacy of both benzimidazoles against human and canine hookworm species occurring in the region need to be assessed. If a suboptimal efficacy of mebendazole was to be confirmed in the country, WHO should consider donating albendazole to Cambodia, whatever the control status of S. stercoralis. Indeed, the lost benefits of continuing to distribute an ineffective drug against one of the most prevalent STH in the country would be unfortunate, particularly in a country that benefits from a well-established and effective control network, was among the first countries to achieve the WHO STH control targets, and has eliminated lymphatic filariasis and trachoma as public health problems; in brief, a country that has a clear capacity to further tackle helminth infections [28, 29, 53, 57, 92, 93, 94].

Conclusions

Both S. stercoralis and hookworm were highly prevalent in the province. Benzimidazoles delivered to control other STH are not effective against S. stercoralis infection and ivermectin should be integrated into STH control programmes to address strongyloidiasis, which is highly prevalent in Cambodia and is associated with significant morbidity. Infection levels of hookworm, despite several years of biannual school-based de-worming with mebendazole, were also high, even among school-aged children. The potential heavy co-morbidity due to overlapping hookworm and S. stercoralis infections should be investigated. Additionally, the effectiveness of the ongoing STH control programme should be assessed, particularly with regard to the efficacy of mebendazole against hookworm infection, including the zoonotic A. ceylanicum, which commonly infects humans in Cambodia. Control programmes should also be assessed in terms of the coverage and compliance achieved. Finally, the high cost of ivermectin, at 10–40 USD per treatment, is a major obstacle to the implementing S. stercoralis PC control in the country. Subsidies or ivermectin donations are needed to start tackling S. stercoralis, which is a public health problem in Cambodia.