Refined stratified-worm-burden models that incorporate specific biological features of human and snail hosts provide better estimates of Schistosoma diagnosis, transmission, and control
- David Gurarie^{1, 2},
- Charles H. King^{2, 3}Email author,
- Nara Yoon^{1} and
- Emily Li^{2}
DOI: 10.1186/s13071-016-1681-4
© The Author(s). 2016
Received: 5 February 2016
Accepted: 5 July 2016
Published: 4 August 2016
Background
Schistosoma parasites sustain a complex transmission process that cycles between a definitive human host, two free-swimming larval stages, and an intermediate snail host. Multiple factors modify their transmission and affect their control, including heterogeneity in host populations and environment, the aggregated distribution of human worm burdens, and features of parasite reproduction and host snail biology. Because these factors serve to enhance local transmission, their inclusion is important in attempting accurate quantitative prediction of the outcomes of schistosomiasis control programs. However, their inclusion raises many mathematical and computational challenges. To address these, we have recently developed a tractable stratified worm burden (SWB) model that occupies an intermediate place between simpler deterministic mean worm burden models and the very computationally-intensive, autonomous agent models.
Methods
To refine the accuracy of model predictions, we modified an earlier version of the SWB by incorporating factors representing essential in-host biology (parasite mating, aggregation, density-dependent fecundity, and random egg-release) into demographically structured host communities. We also revised the snail component of the transmission model to reflect a saturable form of human-to-snail transmission. The new model allowed us to realistically simulate overdispersed egg-test results observed in individual-level field data. We further developed a Bayesian-type calibration methodology that accounted for model and data uncertainties.
Results
The new model methodology was applied to multi-year, individual-level field data on S. haematobium infections in coastal Kenya. We successfully derived age-specific estimates of worm burden distributions and worm fecundity and crowding functions for children and adults. Estimates from the new SWB model were compared with those from the older, simpler SWB with some substantial differences noted. We validated our new SWB estimates in prediction of drug treatment-based control outcomes for a typical Kenyan community.
Conclusions
The new version of the SWB model provides a better tool to predict the outcomes of ongoing schistosomiasis control programs. It reflects parasite features that augment and perpetuate transmission, while it also readily incorporates differences in diagnostic testing and human sub-population differences in treatment coverage. Once extended to other Schistosoma species and transmission environments, it will provide a useful and efficient tool for planning control and elimination strategies.
Keywords
Mathematical models Schistosomiasis control Drug therapy Disease transmissionBackground
Parasitic Schistosoma species pose a significant health burden in many developing countries [1]. Broad-based regional schistosomiasis control and local elimination of parasite transmission have been prioritized in the 2012 London Declaration for Neglected Tropical Diseases (http://unitingtocombatntds.org/resource/london-declaration) and the recent World Health Organization 2020 Roadmap on Neglected Tropical Diseases (NTDs) [2].
The parasite has a complex ecology in which it cycles between human and snail hosts through intermediate larval stages, in a manner that strongly embeds transmission within at-risk sub-tropical and tropical ecosystems [3]. A key feature of Schistosoma infections (similar to other metazoan macro-parasites) is the highly uneven (heterogeneous) distribution of infection burden among its vertebrate host populations, as evident in both experimental and field data [4–6]. Other heterogeneous factors that play important roles in perpetuation of schistosomiasis include variations in local human demographics and exposure frequencies, patchy transmission habitats, and the seasonality of rainfall and temperature factors that affect snail abundance [7].
Modeling of such systems is a challenging task, but to provide more accurate estimates for current control programs, newer models should account for the influential features of in-host biology, transmission environment, diagnostic uncertainties, and the potential efficiency of different control interventions. Conventional approaches based on mean worm burden (MWB) formulations [4, 8–11] have had several shortcomings in this respect. They have used ad-hoc assumptions about worm load distributions and appear to have oversimplified some components of the transmission system. As a result, infection rates in such systems and the modeled impacts of treatment tend to be overestimated [12]. Individual-based modeling approaches (e.g. [13]) could potentially address some of these issues, but individual-based models have significant limitations in terms of accessibility and programming requirements, particularly for large populations.
The stratified worm burden (SWB) approach occupies an intermediate place between MWB and individual-based models, and offers many advantages [12, 14]. Among other features, it provides a natural way to account for worm dispersion in demographically-structured host populations. Our earlier work with SWB [14, 15] was limited in terms of within-host parasite biology, as we had assumed perfect mating and uniform egg-release by all worm male-female pairs, independent of accumulated burden. Here, we refine the earlier SWB model to account for influential components of in-host biology including the aggregated distribution of worm burden, worm mating probabilities, density-dependent worm fecundity, and random features of egg-release [12, 16]. These newly incorporated biological parameters allow us more realistic simulation of diagnostic egg-tests and of environmental egg release and its effect on the force of infection to intermediate host snails. We have developed a new Bayesian calibration procedure that recognizes many uncertainties of modeling infection data based on standard egg-count tests [17–22]. The goal of this calibration approach was to identify the most ‘likely’ model parameter choices consistent with the collected field data. The posterior parameter ensembles for a community could then be used for dynamic simulations of control interventions, incorporating the uncertainties about diagnosis and transmission reflected in the input data. The model/data uncertainties thus yield more robust statistical estimates, including credible ranges for the projected treatment outcomes.
In the current paper, we explain how we have applied the new model and calibration methodology to the field data collected in survey and control studies of S. haematobium in coastal Kenya [23–26]. These data provide a fairly complete demographic coverage of several communities, well-suited for our analysis. Because we had also used this data set in our previous modelling using a simpler SWB model (i.e. without in-host biology [14, 15]), we can compare the two models to demonstrate how inclusion of these biological factors can result in more accurate projections of post-treatment infection outcomes.
Methods
Description of stratified worm burden system with in-host biology
System variables in the SWB model
System variable | Symbols |
---|---|
SWB prevalence strata: | |
k Δw ≤ w < (k + 1)Δw with worm burden increment Δw | \( \begin{array}{c}\hfill \left\{{h}_k(t):k=0,1,\dots \right\}\hfill \\ {}\hfill {\displaystyle {\sum}_k{h}_k=1}\hfill \end{array} \) |
Demographically structured SWB: | |
Child | h _{ k } ^{ C } (t) |
Adult | h _{ k } ^{ A } (t) |
Population densities per unit habitat: | |
Human | H (t) |
Snail (susceptible, infected, patent) | N(t) = x(t) + y(t) + z(t) |
SWB system
Host population H = ∑ _{ k = 0} ^{ n } h _{ k } is divided into burden strata {h _{ k }} by their worm load (w = # adult worms): k Δw ≤ w < (k + 1)Δw for h _{ k }. The partition is determined by worm-step Δw ≥ 1, that serves as hypothetical mating threshold. So h _{0} are infection-free (no mated couples), while for h _{ k } (k ≥ 1) its mated count (expected number of couples) given by function (Eq. 1). The transitions among strata \( \begin{array}{cccccc}\hfill \downarrow {S}_0\hfill & \hfill \hfill & \hfill \downarrow {S}_1\hfill & \hfill \hfill & \hfill \hfill & \hfill \downarrow {S}_n\hfill \\ {}\hfill {h}_0(t)\hfill & \hfill \underset{\gamma_1}{\overset{\lambda }{\rightleftharpoons }}\hfill & \hfill {h}_1(t)\hfill & \hfill \underset{\gamma_2}{\overset{\lambda }{\rightleftharpoons }}\dots \hfill & \hfill \underset{\gamma_n}{\overset{\lambda }{\rightleftharpoons }}\hfill & \hfill {h}_n(t)\hfill \\ {}\hfill \downarrow \mu \hfill & \hfill \hfill & \hfill \downarrow \mu \hfill & \hfill \hfill & \hfill \hfill & \hfill \downarrow \mu \hfill \end{array} \) are determined by force of infection (FOI) λ (= rate of worm accumulation/Δw), resolution rates γ _{ k } = k γ (γ - mean worm mortality), and population turnover rate μ (mortality, maturation, migration, etc.). Source terms S _{ k } represent demographic inputs from related population groups, e.g. for children S _{0} = b _{ H } (birth rate), with S _{ k ≥ 1} = 0 (as all newborns are infection-free); whereas adult sources come from maturing child strata. For the interested reader, a version of the SWB model programmed in Mathematica software is provided as Additional file 1 |
Because low worm burden is very difficult to measure in living humans, there are no accurate estimates of the relevant minimal Δw. Theoretical arguments suggest relatively low values, Δw = 5 [9, 14]. Experimental data from primate infections [27] predicts Δw ≈ 40. Currently, we use an intermediate value of Δw = 10 in our numeric implementation of the SWB system.
Random egg-release by hosts and SWB communities: simulation of egg-test data
Random egg-release
Egg release by mated females and individual hosts depends on worm fecundity ρ _{ k }, and mated-couple count ϕ _{ k } (for h _{ k } -stratum). The former is given by crowding function \( {\rho}_k={\rho}_0\;{e}^{-k/{k}_0} \), with maximal value ρ _{0} and threshold k _{0}. The latter ϕ _{ k } can be estimated by assuming binomial sex-ratio distribution in the “w-strata” (w adult worms), Eq. (1). The predicted egg-release by h _{ k }-hosts, E _{ k } = ρ _{ k } ϕ _{ k }, gives its mean (expected) value used as measure of host infectivity. The actual release should be random (NB) with mean E _{ k } and aggregation r _{ k } = r ϕ _{ k }.
Individual egg-counts-counts by all SWB hosts (strata {h _{ k }}) generate a mixed NB-distribution (4), illustrated in the schematic plot above. Each simulated egg-test of SWB community is then a random sample of size H (sampled pool) drawn from distribution P _{ SW } |
In our SWB model development, simulated (random) community egg-tests were used extensively for model calibration and later for prediction and analysis of control intervention outcomes.
and function E represents average host infectivity of SWB community {h _{ k }}.
Details of the local snail population model
Snail population-transmission dynamics
Dynamic variables for the snail model are population densities (per unit habitat) x: susceptible; y: prepatent; z: patent; N = x + y + z- total. \( \overset{\beta }{\to}\underset{\begin{array}{l}\downarrow \\ {}\nu \end{array}}{x}\underset{\left(1-c\right)r}{\overset{\varLambda }{\rightleftarrows }}\kern0.24em \underset{\begin{array}{l}\downarrow \\ {}\nu \end{array}}{y}\overset{c\;r}{\to}\underset{\begin{array}{l}\downarrow \\ {}\nu \end{array}}{z} \) Basic processes and parameters include (i) snail reproduction (logistic growth) β = β _{0}(x + y)(1 − N/K), with maximal reproduction rate β _{ 0 } and carrying capacity K; (ii) snail mortality v; (iii) snail FOI Λ(determined by human host egg outputs) ; (iv) recovery rate r (prepatency period 1/r) (v) patency conversion fraction c. In population growth term β, only susceptible and prepatent snails (x + y) reproduce. Combined growth-SEI dynamics consists of 3 differential equations \( \begin{array}{l}\frac{dx}{dt}=\beta -\varLambda\;x-\nu\;x+r\left(1-c\right)y\\ {}\frac{dy}{dt}=\varLambda\;x-\left(r+\nu \right)\;y\\ {}\frac{dz}{dt}=c\;r\;y-\nu\;z\end{array} \) Parameter values and ranges for the snail system are given in Table 5. Short-lived larval stages (M, C) equilibrate rapidly at levels proportion to human/snail (H, N) multiplied by their respective infectivity. Specifically, C* = α _{ C } N z; M* = β _{ M } ω H E (6) where \( {\alpha}_C=\frac{\pi_C}{\nu_C} \) (“C-production /patent snail” over “C-mortality”). For miracidia the relevant inputs include environmental egg-release by host population ω H E, ω = human-snail contact rate, H - population size, E - mean host infectivity - egg release (Eq. 5), coefficient \( {\beta}_M=\frac{\sigma_M}{\nu_M} \) (“survival fraction of eggs” over “M - mortality”) |
Here a successful miracidial invasion (Table 4) is followed by the prepatent stage lasting 1/r days, after which a fraction c of prepatent snails convert to the patent/shedding stage (z), while the remaining fraction (1 − c) may resolve infection to return to the susceptible (x) stage. Snail FOI Λ is determined by human infectivity (E), the human population size, and human-snail contact rate, ω.
Human-to-snail force of infection in coupled SWB systems
Human-snail transmission is mediated by two larval stages, cercaria (C) and miracidium (M), which determine snail-to-human FOI (λ) and human-to snail FOI (Λ), respectively. It is convenient to measure all populations (human H, snail N, M, and C) by their densities per unit habitat.
The key inputs in Λ are sporocyst establishment rate Λ_{0} and the transmission coefficient b = αβ _{ M } (product of “miracidium coefficient” β _{ M } times “snail susceptibility” α). At low transmission intensity (H E ≪ 1) function (Eq. 9) is approximately linear \( \left(\varLambda \approx {\varLambda}_0b\omega \frac{H\;E}{N}\right) \) - the conventional form of snail FOI. But unlike a “linear” Λ function, Eq. (9) would saturate at a maximum level = Λ_{0} for large H E. This has important implications for transmission dynamics and model calibration. In general, one could expect higher values of estimated coefficient b, compared to the linear model case. In dynamic simulations, this would yield higher persistence of transmission and a more rapid rate of human reinfection after mass drug administration (MDA) to the human population.
Thus, the basic inputs needed for running a coupled SWB model system are: (i) the biological SWB parameters of worm fecundity ρ(w) and egg-release E _{;} (ii) human and snail population densities H, N, along with their demographic (birth, death, migration) parameters; and (iii) the human exposure/ water contact rate ω, and the resulting operative transmission parameters (α, b).
Calibrating the human SWB system
The first input for calibration is a human egg-test data set (~500 cases) from a given community, or a population subgroup (e.g. age group). The goal of this human-side SWB calibration is to find most likely values of biological (fecundity) parameters ρ _{ B } = {ρ _{0}, w _{0}, r} and transmission λ (= “rate of worm accumulation”/”worm mortality”) that are consistent with test data. Parameter λ is proportional to the mean worm burden of the SWB community in its equilibrium (endemic) state, \( \overline{w}=\lambda \varDelta w \).
For each choice (λ, ρ _{ B }), we simulate an ensemble of random egg-tests outputs to compare with the observed data. Each simulated egg-test involves two random steps: (1) the random selection of subjects from a population sub-group to be tested and (2) the random egg-release by each tested host in each stratum. These two steps are combined via a random sampling of a mixed NB distribution (Eq. 4) with prescribed parameters {λ, ρ _{ B } = (ρ _{0}, k _{0}, r)} (see Table 3). By this approach, we generate an SWB equilibrium {h _{ k }(λ)} from λ and then compute the mean egg-release E _{ k } = ρ _{ k } ϕ _{ k } and aggregation r _{ k } = rϕ _{ k } for each stratum h _{ k }, using the determined biological parameters ρ _{ B }, i.e. \( {\rho}_k={\rho}_0{e}^{-k/{k}_0} \) (fecundity) and Φ _{ k } (mating (Eq. 1)). Three inputs {h _{ k }, E _{ k }, r _{ k }} give rise to the mixed NB-distribution D _{ M } (λ, ρ _{ B }) of (Eq. 4). The simulated community egg-test output is thus a random sample of H subjects (the surveyed pool) drawn from distribution \( {D}_M,{\mathsf{E}}_T=\left\{{e}_1;\dots; {e}_H\right\} \) (e _{ i } - egg-count of i-th test sample).
Here, c _{0} counts negatives (uninfected pool), c _{1} - includes the range E _{1} ≤ e < E _{2}, etc. Different binning choices E _{0} < E _{1} < E _{2} < … are possible depending on the range and distribution of test diagnostics. For S. haematobium, 10 ml urine filtration [21] has typical counts 0 ≤ e ≤ 1000, and egg count values are highly over-dispersed (Fig. 3). A suitable choice in such context is the log-scale E _{ k } = 2^{ k }(k = 1, 2, …, 10), such that the egg-count range, ([0–1,000), would split into 10 log-scale bins.
Simulated egg distribution E _{ S }(λ, ρ _{ B }) (Eq. 10) depends on model parameters, but each output E _{ S } = {c _{0}, c _{1}, …} is random. The same, we expect, should hold for the real test data E _{ D } = {d _{ k }}, due to uncertainties of sampling and diagnostics [17–22]. Our goal is to compare two random samples (E _{ S }; E _{ D }) to assess their “proximity” via a suitable distance-function, d(E _{ S }; E _{ D }). The task is confounded by randomness of both samples, particularly of simulated E _{ S }. To account for this, we assess the “proximity” between the simulated test ensemble \( \mathsf{E}=\mathsf{E}\left(\uplambda, {\uprho}_{\mathrm{B}}\right)=\left\{{\mathrm{E}}_{\mathrm{S}}\right\} \), and observed data, E _{ D }, instead of comparing individual test samples {E _{ S }}. Such a procedure is cast in a Bayesian framework by asking how likely it is to observe a given data set E _{ D } for a particular (parameter choice) ensemble \( \left(\mathsf{E}=\mathsf{E}\left(\lambda, {\rho}_B\right)\right) \). In other words, we ask what is the probability of observing E _{ D } conditioned on \( \mathsf{E}? \).
Calibration proceeds by randomly scanning the parameter space (λ, ρ _{ B }) (“uninformed” prior) and generating a mean-covariance structure for uniformly sampled 4D hypercube in the parameter space: λ ' < λ < λ "; ρ _{0} ' < ρ _{0} < ρ _{0} "; k _{0} ' < k _{0} < k _{0} "; r ' < r < r ".
Once such a mean-covariance test-bed ({Ē(λ, ρ _{ B }), σ(λ, ρ _{ B })}) is computed, any specific test data (E _{ D }) will generate a family of likelihood weights (Eq. 12) on the (λ, ρ _{ B }) -space and give the empirical posterior distribution \( \mathsf{D}=\mathsf{D}\left(\lambda, {\rho}_B\right) \) consistent with E _{ D }.
Figure 4 illustrates the range of likely egg output simulation runs using a fixed, random parameter choice that makes the Ē _{ S }, E _{ D } distribution fairly close.
The above calibration procedure is applied to the youngest age group (children). The adult calibration requires an additional input, namely a SWB - source term coming from maturing children (see Additional file 2). Thus, the adult parameter space has an additional calibrated parameter - pre-adult λ _{ C }, along with adult λ _{ A } and biological adult ρ _{ B } = (ρ _{0}, k _{0}, r). To estimate its likelihood weights, we proceed as above by scanning the extended parameter space (λ _{ C }, λ _{ A }, ρ _{ B }) and generating the adult test-bed {Ē(λ _{ C }, λ _{ A }, ρ _{ B }), σ(λ _{ C }, λ _{ A }, ρ _{ B })}.
Once the mean-covariance test-bed is computed, calibration of any specific data set proceeds straightforwardly. Binned egg-data is substituted into the error function (Eq. 11) to get a family of likelihood weights (Eq. 12), resulting in an (empirical) posterior distribution consistent with the data.
Calibrating the coupled human-snail system’s transmission coefficients
Having calibrated the human side of SWB dynamics, our next task is to combine human and snail infection data to estimate transmission coefficients (α, b) of coupled human-snail systems. In earlier work [14], we developed such a scheme for simplified SWB - snail systems. The current SWB modelling approach required significant modification, as outlined below.
- i)
\( A=\alpha \omega =\frac{\lambda /\varDelta w}{N\;z} \) - snail-to-human transmission
- ii)
\( c=\frac{\nu }{r}\frac{z}{y} \) - patency conversion fraction (estimated from snail prevalences)
- iii)
\( \varLambda =\frac{v\left(v+r\right){y}^{*}}{v-\left(c\;r+v\right){y}^{*}} \) - snail FOI, estimated from snail prevalence data, known ν, r and estimated c
- iv)
\( B=b\omega =\frac{N^{*}\left(\varLambda \right)}{N\;E}1\mathrm{n}\left(\frac{\varLambda_0}{\varLambda_0-\varLambda}\right) \) - human-to-snail transmission in snail FOI (Eq. 9).
Demographic and biological parameters for SWB systems
Parameters | Name | Value |
---|---|---|
Host turnover rates: | ||
Child | μ _{ C } = τ + δ _{ C } (maturation + mortality) | 0.05 + 0.003/year |
Adult | μ _{ A } (mortality) | 0.02 – 0.03/year |
Demographic sources: | ||
Child | S ^{ C } = {b _{ c }, 0, 0, …}; per capita birth rate | b _{ C } = 0.032/year [37] |
Adult | S ^{ A } = τ{h _{0} ^{ C } , h _{1} ^{ C } , …} | |
Mean daily urine release [34]: | ||
Child | U _{ C } = 1100 ml | |
Adult | U _{ A } = 1300 ml | |
Worm turnover rate: | ||
Worm mortality | γ | 0.2/year [50] |
Snail parameters: | ||
Snail mortality | v _{ S } | 2.6/ year |
Recovery/conversion rate | r | \( \frac{1}{4} \) weeks |
Patency conversion fraction | c | 0.05–0.20 |
Rate of sporocyst establishment | Λ_{0} | \( \frac{1}{2} \) weeks |
Adding MDA-based control to the SWB system
The reinitialized system is solved over the prescribed time-range (between two “events”) and the process continues.For more detail, see Fig. 4 of reference [33].
Results
Model calibration
Calibration results for the children’s age group: demographic and infection data with calibrated model parameters (mean ± SD) for 12 Msambweni villages
Villages | V1 | V2 | V3 | V4 | V5 | V6 | V7 | V8 | V9 | V10 | V11 | V12 |
---|---|---|---|---|---|---|---|---|---|---|---|---|
Population | 602 | 286 | 189 | 281 | 353 | 638 | 557 | 921 | 944 | 720 | 815 | 803 |
Prevalence (%) | 71 | 67 | 52 | 51 | 50 | 49 | 43 | 32 | 27 | 25 | 24 | 23 |
Mean Intensity | 126 | 170 | 113 | 116 | 126 | 91 | 77 | 78 | 46 | 48 | 49 | 46 |
Human FOI^{a} | 5.9 ± 1.3 | 5.6 ± 1.4 | 4.5 ± 1.6 | 3.2 ± 1.2 | 4.1 ± 1.5 | 4.2 ± 1.6 | 2.3 ± 0.9 | 2.1 ± 1.3 | 1.8 ± 1.1 | 1.9 ± 1.3 | 2.3 ± 1.5 | 1.4 ± 1.0 |
Maximum fecundity variable, ρ_{0} | 25 ± 8 | 43 ± 11 | 36 ± 13 | 44 ± 13 | 45 ± 13 | 33 ± 13 | 36 ± 12 | 48 ± 15 | 40 ± 15 | 45 ± 15 | 45 ± 15 | 46 ± 14 |
Crowding threshold variable, w_{0} | 116 ± 47 | 127 ± 42 | 118 ± 43 | 123 ± 43 | 123 ± 42 | 118 ± 43 | 123 ± 43 | 128 ± 43 | 125 ± 45 | 130 ± 45 | 130 ± 44 | 129 ± 46 |
Aggregation | 0.03 ± 0.01 | 0.04 ± 0.02 | 0.03 ± 0.02 | 0.05 ± 0.02 | 0.03 ± 0.02 | 0.03 ± 0.02 | 0.06 ± 0.02 | 0.05 ± 0.03 | 0.05 ± 0.03 | 0.04 ± 0.02 | 0.03 ± 0.02 | 0.05 ± 0.03 |
Calibration results for adults: demographic and infection data with calibrated model parameters (mean ± SD) for 12 Msambweni villages
Villages | V1 | V2 | V3 | V4 | V5 | V6 | V7 | V8 | V9 | V10 | V11 | V12 |
---|---|---|---|---|---|---|---|---|---|---|---|---|
Population | 508 | 264 | 189 | 247 | 259 | 530 | 472 | 653 | 738 | 456 | 512 | 746 |
Prevalence (%) | 33 | 24 | 31 | 23 | 27 | 19 | 14 | 13 | 14 | 7 | 13 | 12 |
Mean Intensity | 19 | 11 | 30 | 11 | 25 | 6 | 8 | 10 | 7 | 2 | 10 | 6 |
Human FOI^{a} | 1.6 ± 0.6 | 1.2 ± 0.6 | 1.6 ± 0.6 | 1.2 ± 0.6 | 1.4 ± 0.6 | 1.0 ± 0.6 | 0.9 ± 0.7 | 0.7 ± 0.6 | 0.8 ± 0.6 | 0.5 ± 0.6 | 0.7 ± 0.7 | 0.7 ± 0.6 |
Maximum fecundity variable, ρ_{0} | 11 ± 5 | 4 ± 3 | 11 ± 6 | 6 ± 4 | 10 ± 6 | 5 ± 4 | 11 ± 6 | 12 ± 6 | 8 ± 6 | 11 ± 7 | 13 ± 6 | 11 ± 6 |
Crowding threshold variable, w_{0} | 122 ± 44 | 122 ± 43 | 125 ± 43 | 125 ± 44 | 124 ± 43 | 123 ± 44 | 120 ± 44 | 120 ± 44 | 119 ± 44 | 126 ± 44 | 122 ± 44 | 120 ± 44 |
Aggregation | 0.03 ± 0.02 | 0.05 ± 0.03 | 0.04 ± 0.02 | 0.04 ± 0.02 | 0.04 ± 0.02 | 0.04 ± 0.03 | 0.03 ± 0.02 | 0.04 ± 0.03 | 0.04 ± 0.03 | 0.03 ± 0.02 | 0.03 ± 0.02 | 0.04 ± 0.02 |
Pre-adult FOI | 3.7 ± 2.3 | 3.7 ± 2.3 | 4.0 ± 2.4 | 3.7 ± 2.3 | 3.8 ± 2.4 | 3.7 ± 2.2 | 3.7 ± 2.3 | 3.8 ± 2.3 | 3.8 ± 2.3 | 3.3 ± 2.2 | 3.9 ± 2.3 | 3.8 ± 2.3 |
Parameters and their expected ranges based on calibration
Parameter | Symbol [units] | Value range |
---|---|---|
Force of infection (FOI) | λ [worm/year] | Child: (0, 8) |
Adult: (0, 3) | ||
Maximum egg release | ρ _{0} [egg/female] | Child: (10, 70) |
Adult: (1, 25) | ||
Crowding threshold | w _{0} [worm] | (50, 200) |
Egg aggregation^{a,b} | r ^{a} | (0, 0.1) |
Child FOI for adult calibration | λ _{ C } [worm/year] | (0, 8) |
Posterior distributions and their likelihood weights (Eq. 12) play important roles in our analysis and the control simulations reported below. All statistical outputs (means, correlations, quantiles, etc.) were computed relative to ensemble \( \mathsf{D} \). Thus for MDA simulations, we ran multiple treatment histories using a suite of likely parameter choices (for a given community) based on \( \mathsf{D} \), and assigned each output its respective likelihood weight.
Not unexpectedly, fecundity parameters exhibited fairly consistent values across the region with nearly horizontal linear fits for these parameter values across villages (Fig. 5). This suggested that hosts carrying comparable worm burden release similar egg-counts regardless of residing in high vs. low transmission areas. The only significant difference in parameter estimates comes between age groups, with children showing much higher, per-worm fecundity than adults (ρ _{ C } ≫ ρ _{ A }). Consistent values of biological parameters across the region allow us to combine the 12 local village distributions of (ρ _{0}, w _{0}, r) into a single posterior ensemble, \( {\mathsf{D}}_B \). This “biological ensemble” \( {\mathsf{D}}_B \) is then used in the subsequent analysis and simulation of coupled human-snail systems. Calibrated child and adult FOIs (λ_{C} ; λ_{A}) show consistently higher values for children than for adults across the region (see Fig. 6).
Estimates for the density-dependent crowding effect
Predicting prevalence and intensity curves
Model validation
Another validation test involved a functional relation between egg-test prevalence P _{ E }, FOI λ or its inverse function λ(P _{ E }), and predicted mean infection intensity (= mean egg-count). Model equations (Eq. 13) gives both P _{ E }(λ, ρ _{ B }) and M _{ E }(λ, ρ _{ B }) as functions of λ and biological parameters ρ _{ B } = (ρ _{0}, w _{0}, r). To test consistency of such relations with village data across the region, we took a random selection of parameters {ρ _{ B }} drawn from the biological posterior \( {\mathsf{D}}_B \) and for each choice computed M _{ E }(λ, ρ _{ B }) and P _{ E }(λ, ρ _{ B }) -curves and their envelopes, shown in Fig. 8a, b. We found the data points lying well within the margins of the predicted mean and prevalence-functions. [N.B. These functional relations (Eq. 13) illustrated in Fig. 8b are useful for estimating an unknown SWB parameter λ in situations where the available data are incomplete, e.g. when only aggregated, community-level egg prevalence data are available instead of individual-level egg test data].
Projecting the impact of MDA-based control
For this step, we applied our calibrated model to project MDA-control effects and post-treatment prevalence in one of the twelve Msambweni villages, Milalani, which was more intensively studied for the impact of MDA. The all-ages data used for analysis were collected in three village-wide surveys from 2000 (pretreatment baseline), 2003 (2 years post-treatment) and 2009 (six years post-treatment). The community-wide MDA in 2000 had a 79 % treatment coverage whereas the 2003 treatment coverage was only 41 %. The baseline (pretreatment) data served to calibrate the system, while the two post-treatment data sets were used to test model predictions. The coupled human-snail model consisted of two SWB groups (children, adults) linked to a single hypothetical snail site with a snail infection level approximating the average of five known Msambweni snail sites; SEI snail prevalence values in this experiment were taken as {x*, y*, z*} = {.63,.35,.02} based on field observations of bulinid snail PCR positivity for S. haematobium DNA [35] used to determine the number of ‘exposed’ snails and the observed annual frequencies of shedding snails [24, 36] for ‘infectious’ snails.
For our long term MDA prediction, we also scaled in overall population growth based on Kenyan demographics [37] and inter-seasonal variations of snail density over the 9-year study period. An ensemble of 150 likely calibrated parameter choices was drawn from the Milalani posterior and their 9-year histories computed. At each time, t, we took dynamic solutions and used equations (Eq. 13) to estimate the corresponding community egg-test results (prevalence and intensity) for child and adult age groups. We also ran this simulation for several values of the snail FOI -parameter rate, Λ_{0} (sporocyst establishment rate), ranging from 0.5 to 2 weeks.
Comparison between simple and advanced SWB models: parameter estimation and control predictions
The key for analysis and calibration of coupled human-snail systems are two forces of infection: snail-to-human λ and human-to-snail Λ. Both depend on snail/ human infectivity and the population densities of host and vector. For simple SI (susceptible-infected) snail system, λ is proportional to infected (patent) snail prevalence λ ∝α y with transmission coefficient a = “mean rate of worm accumulation in host” and infected (patent) snail prevalence y.
In the simple SWB system, snail FOI is taken proportional to mean human ‘infectivity’ = mean egg-release E by human hosts into the environment, Λ = bE, with transmission coefficient b. Transmission coefficients \( \alpha \), b combine multiple factors and processes (population densities, human-snail contact rates, intermediate larval stages, etc.). Human infectivity function E depends on details of on worm aggregation and in-host biology.
This procedure could be extended to demographically and/or geographically linked SWB systems (see [14, 15]). No uncertainties entered the simple SWB (or its calibration), but explicit algebraic formulae allowed one to relate data noise to parameter estimation.
In comparing the predicted FOI curves (P _{ E }(λ, ρ _{ B }) and P _{ W }(λ)) for the two SWB systems (old and new), only the latter, P _{ W }, exists for the simple SWB, as no distinction was made there between worm-based and egg-test-based prevalence. For the new SWB, Fig. 8b shows quantile envelopes of P _{ E } curves sampled over a range of biological parameters ρ _{ B } (biological posterior). In general, we expect P _{ E }(λ) < P _{ W }(λ), as worm-carrying strata could contribute to zero egg count. For the simpler SWB, the red curve in Fig. 8b shows its significant departure from the median (and surrounding quantile envelopes) of the new SWB that incorporated host-worm biological interactions. We conclude that the old SWB significantly underestimated FOI λ ^{*} and transmission rate a (Eq. 15), while overestimating fecundity factor ρ (Eq. 14).
To explore possible effect of such discrepancies on MDA control prediction, we took the above 9-year study for Milalani and compared simple SWB (dashed red line) with new calibrated envelope prediction in Fig. 10. Predicted prevalence of both models is reasonably close (within uncertainty envelopes), but the predicted infection intensity for children is underestimated using the simpler SWB (the dashed red line outside the newly calibrated envelope of likely values).
Discussion
The newer calibrated SWB modeling approach appears well suited for simulating the effects of control interventions, particularly the effects of mass drug therapy. Other data inputs and other control strategies could easily be implemented within our setup, such as targeting treatment to specific populations, and modeling the efficiency of different post-treatment surveillance strategies. In the present analysis, we examined one case of long-term MDA outcomes in a Kenyan study site (population ~2,000) to validate our model in a dynamic setting and assess its predictive accuracy. Predicted relaxation patterns (means, envelopes, and quantiles) were found in good agreement with the observed data. Additional evidence comes from recent work [33] where our model and methodology was applied to program data from the Schistosomiasis Consortium for Operational Research and Evaluation (SCORE) on S. haematobium control from Mozambique. While this Mozambique data covered a wide spectrum of communities and control strategies, it was limited in terms of the number and age range of persons tested. To fill in some of the missing data gaps, we utilized certain parameter estimates from the Kenyan data studied here, assuming that similar population groups in both countries share comparable ‘biological’ infection parameters in terms of worm fecundity and density dependence. These calibrated inputs allowed us to build coupled SWB-snail systems for Mozambique communities and accurately simulate the MDA outcomes of the SCORE project.
Typical diagnostic tests for Schistosoma infection (based on egg counting in stool or urine) exhibit highly uneven distributions in host populations. These heterogeneities exist not only for broader communities, but for specific demographic groups that are assumed to be nearly the same in terms of risk. We conclude that several factors contribute to overdispersion of test results, among them uneven worm load due to varying exposure and/or host susceptibility [6], and irregular (clustered) egg release into human excreta [16]. Conventional population-based approaches to modeling (mean worm burden (MWB) models [8]) either ignore uneven burden (taking its population mean) or impose ad-hoc assumptions on worm distribution (e.g. the negative binomial [12]). Either approach has severe limitations (see [12]) that can reduce the utility of the model and the accuracy and robustness of its predictions. While autonomous agent, individual-based model simulations can allow for multiple heterogeneities [15], this alternative type of model has limited capacity in term of population size and program implementation on desktop/laptop platforms.
The SWB approach bridges the gap between these two types of models. It gives a consistent, assumption-free account of uneven worm load and naturally accommodates essential in-host biology, including worm mating probability and density-dependent reduction in fecundity. While the resulting SWB systems have more variables (depending on stratification), there are only a few model parameters per stratum that need to be calibrated, similar to the requirements for a low-dimensional MWB model. We note that promiscuous mating by female worms would enhance the continuation of transmission following MDA if, as generally seen, only partial elimination of worms is achieved with treatment. We have discussed the issue of mating patterns in some depth in our previous paper [12].
To better mimic the dynamics of human-to-snail-to-human parasite transmission, we have revisited and revised conventional approaches to modeling snail population and infection in our coupled SWB modeling systems. Typically, in MWB and related models, the parasite’s short-lived larval stages are not modeled but rather incorporated into an effective ‘force of infection’ (FOI) term, λ, for snail-to-human transmission, and Λ, for human-to-snail transmission. The latter, Λ, is often taken be proportional to human-to-snail infectivity in terms of cumulative Schistosoma egg release by the local human community, with a fraction of these eggs converting to miracidia to invade susceptible snails (see e.g. [9]). A new, closer look at the miracidium snail invasion process reveals a more likely nonlinear (saturated) form of snail FOI and sporocyst establishment [32]. The resulting estimates of human-to-snail transmission could provide an explanation for markedly different re-infection rates in some post-MDA communities [38] and the leveraged impact of human in-migration on persistence of transmission [39–41].
To better project future control program outcomes in terms of present-day data, we have developed a Bayesian calibration procedure for our model based on simulating the recognized imperfections of diagnosing infection based on egg-count data [17–22]. Other factors believed to be critical in accurate forecasting of Schistosoma prevalence include human age-group differences in exposure and susceptibility to infection [42–44], density-dependent (crowding) effects on egg production per worm [30, 45], limitations on mating success among adult schistosomes [4, 46], and the development of anti-fecundity immunity among older patients [47]. In our current SWB model, which included these factors [12], we found better calibration for the model in terms of projecting treatment and reinfection outcomes. The result of our calibration procedure is a posterior ensemble of likely SWB community values consistent with a given data set. The posterior distribution of parameter values for a given SWB community/group can be used to generate multiple community actualizations (based on (λ, ρ _{ B }) - choices) in order to simulate the range of likely outcomes. Each outcome is assigned a significance level determined by its likelihood weight. Thus any data/model uncertainties are propagated into “prediction uncertainty”. In most dynamic simulations, e.g. MDA control, these uncertainties can then be shown as prediction envelopes of possible outcomes.
We have applied the above calibration scheme to a specific data set for communities in coastal Kenya, where only S. haematobium is endemic. While the Kenyan communities differed markedly in terms of their risk and infection levels, we found their age-specific biological parameters ρ _{ B } confined within the same close range, regardless of transmission intensity. This result supported our hypothesis on the constancy of in-host worm biology (mating, fecundity) and its parameterization. It was notable that the estimated crowding function (density-dependent fecundity) was different for child and adult groups, which appears to be in accordance with recent findings about the acquisition of anti-fecundity immunity in primates and humans [47]. Of note, our calibrated aggregation parameter r (Table 6) is also consistent with estimates of Hubbard et al. [16] for Schistosoma japonicum infection. A limitation of the present paper is its focus on S. haematobium (and its transmission features) in calibration of model predictions. However, work is in progress to repeat calibration and testing for S. mansoni-control projects in Kenya and Uganda, which should allow comparison of the estimated biological parameters for each species and help to determine if model recalibration is necessary for different species and for different ecological settings.
Conclusions
The SWB provides an efficient, flexible, and viable approach for modeling Schistosoma transmission and control among stratified populations in simple and complex environments. SWB allows for inclusion of in-host biological factors and limitations of diagnostics, and is applicable to a broad range of treatment strategies. Most helpful to program managers, these new features allow us to predict diagnostic egg-test results for modeled SWB population subgroups and for communities at-large. Where only partial diagnostic data are available, the curves in Fig. 8 can serve to estimate parameters of transmission for program outcomes predictions.
This work is being extended to treatment projections for large-scale treatment trials currently implemented in both S. mansoni- and S. haematobium-endemic areas. For the near future, as part of the ongoing NTD Modelling Consortium project [48], our refined SWB model will be further validated against a new data and directly compared to the more traditional deterministic model of our consortium partners [49]. Fitted model predictions will be compared for likelihood and precision using two large data sets from recent control programs in sub-Saharan Africa: (i) the 2003–2006 S. mansoni data from the Ugandan National Schistosomiasis Control Programme in the African Great Lakes region, and (ii) 2010–2015 data from the SCORE/SCI multi-village operational research trial on S. haematobium control in Mozambique, evaluated in our previous paper [33]. Overall, we expect that the methodology developed in the current paper has a broad scope of applications for different Schistosoma species and more generally, for helminth/macroparasites infections where in-host biology plays an important role.
Abbreviations
FOI, force of infection; MDA, mass drug administration; MWB, mean worm burden model; NB, negative binomial distribution; NTD, neglected tropical diseases; PDF, probability density function; SD, standard deviation of the mean; SWB, stratified worm burden model
Declarations
Acknowledgements
We thank our colleagues R. Alsallaq, A. Galvani, D. Durham, M. Ndeffo Mbah, and E. Gurarie for useful inputs and stimulating discussion.
Funding
This work was funded by the Schistosomiasis Consortium for Operational Research and Evaluation (SCORE), based at the University of Georgia, USA, and by the Children’s Investment Fund Foundation (UK) (“CIFF”) through a grant to the Neglected Tropical Diseases Modelling Consortium at Warwick University, UK. The views, opinions, assumptions or any other information set out in this study are solely those of the authors and should not be attributed to CIFF or any person connected with CIFF. The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
Availability of data and materials
The data used in this study for model calibration and validation are included as Additional file 5.
Authors’ contributions
DG, CHK, NY, EL conceived of the study, and participated in its design, performance, and coordination and helped to draft the manuscript. All authors read and approved the final manuscript.
Competing interests
The authors declare that they have no competing interests.
Consent for publication
Not applicable.
Ethics approval and consent to participate
This project re-used anonymized human data from published research surveys [23, 25]. Those surveys were performed with written informed consent of the participants under supervision of the University Hospitals-Case Medical Center IRB (protocol 11-07-42), Cleveland, Ohio, and the Kenya Medical Research Institute Ethical Review Committee (protocol non-SSC #087), Nairobi. Kenya.
Open AccessThis article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.
Authors’ Affiliations
References
- Hotez PJ, Alvarado M, Basanez MG, Bolliger I, Bourne R, Boussinesq M, et al. The global burden of disease study 2010: interpretation and implications for the neglected tropical diseases. PLoS Negl Trop Dis. 2014;8(7), e2865. doi:10.1371/journal.pntd.0002865.View ArticlePubMedPubMed CentralGoogle Scholar
- Savioli L, Daumiere D. Accelerating work to overcome the global impact of neglected tropical diseases: A roadmap for implementation. Geneva: World Health Organization; 2012.Google Scholar
- Colley DG, Bustinduy AL, Secor WE, King CH. Human schistosomiasis. Lancet. 2014;383:2253–64. doi:10.1016/S0140-6736(13)61949-2.View ArticlePubMedPubMed CentralGoogle Scholar
- May RM. Togetherness among schistosomes: Its effects on the dynamics of infection. Math Biosci. 1977;35:301–43.View ArticleGoogle Scholar
- Nåsell I, Hirsch WM. The transmission dynamics of schistosomiasis. Commun Pure Appl Math. 1973;26(4):395–453.View ArticleGoogle Scholar
- Shaw DJ, Grenfell BT, Dobson AP. Patterns of macroparasite aggregation in wildlife host populations. Parasitology. 1998;117(Pt 6):597–610.View ArticlePubMedGoogle Scholar
- Bavia ME, Hale LF, Malone JB, Braud DH, Shane SM. Geographic information systems and the environmental risk of schistosomiasis in Bahia, Brazil. Am J Trop Med Hyg. 1999;60(4):566–72.PubMedGoogle Scholar
- MacDonald G. The dynamics of helminth infections, with special reference to schistosomes. Trans R Soc Trop Med Hyg. 1965;59(5):489–506.View ArticlePubMedGoogle Scholar
- Anderson RM, May RM. Infectious diseases of humans. Dynamics and control. New York: Oxford University Press; 1991.Google Scholar
- Crofton HD. A quantitative approach to parasitism. Parasitology. 1971;62:179–93.View ArticleGoogle Scholar
- Bradley DJ. Regulation of parasite populations. A general theory of the epidemiology and control of parasitic infections. Trans R Soc Trop Med Hyg. 1972;66(5):697–708.View ArticlePubMedGoogle Scholar
- Gurarie D, King CH. Population biology of Schistosoma mating, aggregation, and transmission breakpoints: More reliable model analysis for the end-game in communities at risk. PLoS One. 2014;9(12), e115875. doi:10.1371/journal.pone.0115875.View ArticlePubMedPubMed CentralGoogle Scholar
- Cornell SJ. Modelling stochastic transmission processes in helminth infections. In: Michael E, Spear RC, editors. Modelling parasite transmission and control. New York: Springer; 2010. p. 66–78.View ArticleGoogle Scholar
- Gurarie D, King CH, Wang X. A new approach to modelling schistosomiasis transmission based on stratified worm burden. Parasitology. 2010;137(13):1951–65.View ArticlePubMedPubMed CentralGoogle Scholar
- Wang X, Gurarie D, Mungai PL, Muchiri EM, Kitron U, King CH. Projecting the long-term impact of school- or community-based mass-treatment interventions for control of Schistosoma infection. PLoS Negl Trop Dis. 2012;6(11), e1903. doi:10.1371/journal.pntd.0001903.View ArticlePubMedPubMed CentralGoogle Scholar
- Hubbard A, Liang S, Maszle D, Qiu D, Gu X, Spear RC. Estimating the distribution of worm burden and egg excretion of Schistosoma japonicum by risk group in Sichuan Province, China. Parasitology. 2002;125(Pt 3):221–31.PubMedGoogle Scholar
- Carabin H, Budke CM, Cowan LD, Willingham 3rd AL, Torgerson PR. Methods for assessing the burden of parasitic zoonoses: echinococcosis and cysticercosis. Trends Parasitol. 2005;21(7):327–33.View ArticlePubMedGoogle Scholar
- de Vlas SJ, Engels D, Rabello AL, Oostburg BF, Van Lieshout L, Polderman AM, et al. Validation of a chart to estimate true Schistosoma mansoni prevalences from simple egg counts. Parasitology. 1997;114(Pt 2):113–21.View ArticlePubMedGoogle Scholar
- de Vlas SJ, Gryseels B. Underestimation of Schistosoma mansoni prevalences. Parasitol Today. 1992;8(8):274–7.View ArticlePubMedGoogle Scholar
- Savioli L, Hatz C, Dixon H, Kisumku UM, Mott KE. Control of morbidity due to Schistosoma haematobium on Pemba Island: egg excretion and hematuria as indicators of infection. Am J Trop Med Hyg. 1990;43:289–95.PubMedGoogle Scholar
- Warren KS, Arap Siongok TK, Hauser HB, Ouma JH, Peters PAS. Quantification of infection with Schistosoma haematobium in relation to epidemiology and selective population chemotherapy. I. Minimal number of daily egg counts in urine necessary to establish intensity of infection. J Infect Dis. 1978;138:849–55.View ArticlePubMedGoogle Scholar
- Mwinzi PN, Kittur N, Ochola E, Cooper PJ, Campbell Jr CH, King CH, et al. Additional evaluation of the Point-of-Contact Circulating Cathodic Antigen assay for Schistosoma mansoni infection. Front Public Health. 2015;3:48. doi:10.3389/fpubh.2015.00048.View ArticlePubMedPubMed CentralGoogle Scholar
- Clennon JA, Mungai PL, Muchiri EM, King CH, Kitron U. Spatial and temporal variations in local transmission of Schistosoma haematobium in Msambweni, Kenya. Am J Trop Med Hyg. 2006;75(6):1034–41.PubMedGoogle Scholar
- Kariuki HC, Clennon JA, Brady MS, Kitron U, Sturrock RF, Ouma JH, et al. Distribution patterns and cercarial shedding of Bulinus nasutus and other snails in the Msambweni area, Coast Province, Kenya. Am J Trop Med Hyg. 2004;70(4):449–56.PubMedGoogle Scholar
- King CH, Blanton RE, Muchiri EM, Ouma JH, Kariuki HC, Mungai P, et al. Low heritable component of risk for infection intensity and infection-associated disease in urinary schistosomiasis among Wadigo village populations in Coast Province, Kenya. Am J Trop Med Hyg. 2004;70(1):57–62.PubMedGoogle Scholar
- Muchiri EM, Ouma JH, King CH. Dynamics and control of Schistosoma haematobium transmission in Kenya: an overview of the Msambweni Project. Am J Trop Med Hyg. 1996;55(5 Suppl):127–34.PubMedGoogle Scholar
- Wilson RA, van Dam GJ, Kariuki TM, Farah IO, Deelder AM, Coulson PS. The detection limits for estimates of infection intensity in schistosomiasis mansoni established by a study in non-human primates. Int J Parasitol. 2006;36(12):1241–4.View ArticleGoogle Scholar
- Nasell I. Mating for schistosomes. J Math Biol. 1978;6(1):21–35.View ArticlePubMedGoogle Scholar
- Anderson RM, Medley GF. Community control of helminth infections of man by mass and selective chemotherapy. Parasitology. 1985;90(Pt 4):629–60.View ArticlePubMedGoogle Scholar
- Medley G, Anderson RM. Density-dependent fecundity in Schistosoma mansoni infections in man. Trans R Soc Trop Med Hyg. 1985;79(4):532–4.View ArticlePubMedGoogle Scholar
- Crews AE, Yoshino TP. Schistosoma mansoni: effect of infection on reproduction and gonadal growth in Biomphalaria glabrata. Exp Parasitol. 1989;68(3):326–34.View ArticlePubMedGoogle Scholar
- Thiele EA, Minchella DJ. Molecular assessment of trematode co-infection and intraspecific competition in molluscan intermediate hosts. Mol Biochem Parasitol. 2013;187(1):52–9. doi:10.1016/j.molbiopara.2012.12.003.View ArticlePubMedGoogle Scholar
- Gurarie D, Yoon N, Li E, Ndeffo-Mbah M, Durham D, Phillips AE, et al. Modelling control of Schistosoma haematobium infection: predictions of the long-term impact of mass drug administration in Africa. Parasit Vectors. 2015;8(1):529. doi:10.1186/s13071-015-1144-3.View ArticlePubMedPubMed CentralGoogle Scholar
- Hesse A, Classen A, Knoll M, Timmermann F, Vahlensieck W. Dependence of urine composition on the age and sex of healthy subjects. Clin Chim Acta. 1986;160(2):79–86.View ArticlePubMedGoogle Scholar
- Hamburger J, Hoffman O, Kariuki HC, Muchiri EM, Ouma JH, Koech DK, et al. Large-scale, polymerase chain reaction-based surveillance of Schistosoma haematobium DNA in snails from transmission sites in coastal Kenya: A new tool for studying the dynamics of snail infection. Am J Trop Med Hyg. 2004;71:765–73.PubMedGoogle Scholar
- Sturrock RF, Kinyanjui H, Thiongo FW, Tosha S, Ouma JH, King CH, et al. Chemotherapy-based control of schistosomiasis haematobia. 3. Snail studies monitoring the effect of chemotherapy on transmission in the Msambweni area, Kenya. Trans R Soc Trop Med Hyg. 1990;84(2):257–61.View ArticlePubMedGoogle Scholar
- The World Bank. World development indicators. 2015.Google Scholar
- Kahama AI, Vennervald BJ, Kombe Y, Kihara RW, Ndzovu M, Mungai P, et al. Parameters associated with Schistosoma haematobium infection before and after chemotherapy in school children from two villages in the coast province of Kenya. Trop Med Int Health. 1999;4(5):335–40.View ArticlePubMedGoogle Scholar
- Fenwick A, Jorgensen TA. The effect of a control programme against Schistosoma mansoni on the prevalence and intensity of infection on an irrigated sugar estate in northern Tanzania. Bull World Health Organ. 1972;47(5):579–86.PubMedPubMed CentralGoogle Scholar
- Macdonald F, Clarke Vde V, Gaddie P, Atkinson G. Report on a large-scale attempt at control of bilharziasis by combined mass treatment and intensive snail control. Cent Afr J Med. 1973;19:22–32.Google Scholar
- Gautret P, Mockenhaupt FP, von Sonnenburg F, Rothe C, Libman M, Van De Winkel K, et al. Local and international implications of schistosomiasis acquired in Corsica, France. Emerg Infect Dis. 2015;21(10):1865–8. doi:10.3201/eid2110.150881.View ArticlePubMedPubMed CentralGoogle Scholar
- Abel L, Demenais F, Prata A, Souza AE, Dessein A. Evidence for the segregation of a major gene in human susceptibility/resistance to infection by Schistosoma mansoni. Am J Hum Genet. 1991;48:959–70.PubMedPubMed CentralGoogle Scholar
- Barbour AD. The importance of age and water contact patterns in relation to Schistosoma haematobium infection. Trans R Soc Med. 1985;79:151–3.View ArticleGoogle Scholar
- Chandiwana SK, Woolhouse ME. Heterogeneities in water contact patterns and the epidemiology of Schistosoma haematobium. Parasitology. 1991;103(Pt 3):363–70.View ArticlePubMedGoogle Scholar
- Polman K, De Vlas SJ, Van Lieshout L, Deelder AM, Gryseels B. Evaluation of density-dependent fecundity in human Schistosoma mansoni infections by relating egg counts to circulating antigens through Deming regression. Parasitology. 2001;122(Pt 2):161–7.PubMedGoogle Scholar
- May RM, Woolhouse ME. Biased sex ratios and parasite mating probabilities. Parasitology. 1993;107(Pt 3):287–95.View ArticlePubMedGoogle Scholar
- Wilson S, Jones FM, van Dam GJ, Corstjens PL, Riveau G, Fitzsimmons CM, et al. Human Schistosoma haematobium antifecundity immunity is dependent on transmission intensity and associated with immunoglobulin G1 to worm-derived antigens. J Infect Dis. 2014;210(12):2009–16. doi:10.1093/infdis/jiu374.View ArticlePubMedPubMed CentralGoogle Scholar
- Hollingsworth TD, Adams ER, Anderson RM, Atkins K, Bartsch S, Basanez MG, et al. Quantitative analyses and modelling to support achievement of the 2020 goals for nine neglected tropical diseases. Parasit Vectors. 2015;8:630. doi:10.1186/s13071-015-1235-1.View ArticlePubMedPubMed CentralGoogle Scholar
- Anderson RM, Turner HC, Farrell SH, Yang J, Truscott JE. What is required in terms of mass drug administration to interrupt the transmission of schistosome parasites in regions of endemic infection? Parasit Vectors. 2015;8:553. doi:10.1186/s13071-015-1157-y.View ArticlePubMedPubMed CentralGoogle Scholar
- Anderson RM, May RM. Herd immunity to helminth infection and implications for parasite control. Nature. 1985;315(6019):493–6.View ArticlePubMedGoogle Scholar
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