Optimal methods for fitting probability distributions to propagule retention time in studies of zoochorous dispersal
© Viana et al. 2016
Received: 7 October 2015
Accepted: 13 January 2016
Published: 1 February 2016
Propagule retention time is a key factor in determining propagule dispersal distance and the shape of “seed shadows”. Propagules dispersed by animal vectors are either ingested and retained in the gut until defecation or attached externally to the body until detachment. Retention time is a continuous variable, but it is commonly measured at discrete time points, according to pre-established sampling time-intervals. Although parametric continuous distributions have been widely fitted to these interval-censored data, the performance of different fitting methods has not been evaluated. To investigate the performance of five different fitting methods, we fitted parametric probability distributions to typical discretized retention-time data with known distribution using as data-points either the lower, mid or upper bounds of sampling intervals, as well as the cumulative distribution of observed values (using either maximum likelihood or non-linear least squares for parameter estimation); then compared the estimated and original distributions to assess the accuracy of each method. We also assessed the robustness of these methods to variations in the sampling procedure (sample size and length of sampling time-intervals).
Fittings to the cumulative distribution performed better for all types of parametric distributions (lognormal, gamma and Weibull distributions) and were more robust to variations in sample size and sampling time-intervals. These estimated distributions had negligible deviations of up to 0.045 in cumulative probability of retention times (according to the Kolmogorov–Smirnov statistic) in relation to original distributions from which propagule retention time was simulated, supporting the overall accuracy of this fitting method. In contrast, fitting the sampling-interval bounds resulted in greater deviations that ranged from 0.058 to 0.273 in cumulative probability of retention times, which may introduce considerable biases in parameter estimates.
We recommend the use of cumulative probability to fit parametric probability distributions to propagule retention time, specifically using maximum likelihood for parameter estimation. Furthermore, the experimental design for an optimal characterization of unimodal propagule retention time should contemplate at least 500 recovered propagules and sampling time-intervals not larger than the time peak of propagule retrieval, except in the tail of the distribution where broader sampling time-intervals may also produce accurate fits.
The probability distribution of biological variables is of great importance for modeling and understanding biological phenomena, including the mechanistic basis of ecological processes. Mechanistic models are widely used in seed dispersal ecology (used here as a general term for the dispersal ecology of dormant propagules, including spores, resting eggs and cysts of plants, animals and fungi), as propagule movement is often difficult to track [1–5].
A considerable part of the Earth’s biota does not actively move. Instead, they produce dormant propagules that rely on several types of vectors for their dispersal, such as wind, water and animals [3, 6–10]. Among the various vectors, animals such as birds and mammals disperse a great variety of propagules belonging to different species [8, 10–12]. Propagules are dispersed either externally, entangled in the fur or feathers (“epizoochory” hereafter), or internally, following ingestion and while transiting through the animal’s gut (“endozoochory” hereafter).
A key element in the study of animal-mediated dispersal is the estimation of the distance at which propagules are dispersed. Dispersal distance (D) is usually estimated as the product of the vector movement rate (V) and the retention time (R) of ingested or attached propagules (D = V × R). The distribution of dispersal distances, i.e. the dispersal kernel, is a major determinant of the spatial distribution of individuals, populations and species, thus its accurate estimation is of vital importance for studying and modeling metapopulation and metacommunity dynamics [8, 9, 13], as well as the distributions and expansion rates of species [3, 14, 15]. For example, many species distribution models (SDMs), which are used to model how species are distributed along niche gradients, incorporate dispersal kernels to predict range expansions or shifts under different scenarios of environmental change and estimate realistic distributions according to the species’ dispersal potential [16, 17].
Together with the vector’s movement behaviour, propagule retention time has been found to critically affect several properties of propagule dispersal kernels such as the range and frequency of dispersal events, thus the probability of long distance dispersal [4, 18]. Therefore, the accurate characterization of retention times is of fundamental importance for avoiding the magnification of biases already introduced by assumptions about vector movement when estimating propagule dispersal kernels. This is the reason why numerous empirical studies have investigated the different factors affecting propagule retention time, such as the size and shape of plant propagules [19, 20], the developmental stage of animal propagules , or the morphology [4, 22, 23], digestive physiology [24, 25], and activity [26, 27] of animal vectors.
However, obtaining continuous measurements of propagule retention time is, in most cases, extremely difficult owing to the ample time span and variable grain required (from minutes to several days, depending on the animal vector and propagule type), as well as monitoring interferences on the animal vector. In endozoochory studies, the most common strategy to measure retention time is to force-feed captive animals and collect their droppings at given time intervals, often of varying length [e.g., 24, 28]. Similarly, the usual practice in epizoochory studies is to record propagule attachment time at given time intervals, by measuring the number of propagules that remain attached to the fur of captive or semi-captive animals [29, 30], as well as to experimental coats , from a sample of propagules placed there by hand at the beginning of the experiment. In both cases, propagule retention time (i.e., defecation or detachment time) is recorded as a frequency at the end of given time intervals, thus as a series of interval-censored data.
Nevertheless, the censored nature of these data is usually not taken into account in studies of animal-mediated propagule dispersal (but see ). Although this systematic uncertainty on the precise moment of propagule deposition can severely bias the estimation of dispersal distance, fitting procedures used to characterize the distribution of retention times usually assign the frequency of retrieval to the collection time (i.e., to the upper bound of the time interval). Moreover, in most cases the fitting method is not accurately reported or insufficiently described [e.g. 5, 18, 32–36]. We compared the accuracy and robustness of different methods in fitting continuous probability distributions to propagule retention-time data. Because propagule retention-time data typically show right-skewed distributions with an initial peak (corresponding to the distribution mode) followed by a steep decrease and a long tail, we considered three parametric distributions commonly used to characterize these data: the lognormal, gamma and Weibull distributions. We assessed the performance of five different fitting methods. In the first three methods, we fitted parametric probability distributions to empirical distributions using either the (i) lower, (ii) mid or (iii) upper bounds of the sampling intervals as the data points; and in the other two methods, we fitted cumulative parametric distributions to (upper-bound) data arranged as empirical cumulative distributions, using two different procedures: (iv) maximum likelihood (CD-ML) and (v) non-linear least squares (CD-NLS). To assess the performance of these different methods, we applied them to a simulated dataset (based on empirical distributions; see “Methods” section) and compared the resulting parameter estimates and functions to the original ones. In addition, we assessed the robustness of the five fitting methods to variation in the distribution type (lognormal, gamma and Weibull) or parameter values of the original distribution (from which the simulated dataset was sampled), in the sample size (i.e., number of uptake propagules) and in the length of sampling time-intervals used to generate the simulated dataset.
Variation in probability distribution
Variation in sample size
Variation in sampling interval
Impact of fitting method on estimates of propagule dispersal kernels
Biases introduced by the choice of methods used to fit propagule retention time, on the dispersal kernels of two plant species (Potamogeton pectinatus Pp, and Scirpus lacustris Sl) dispersed by the same vector species (mallard Anas platyrhyncos)
The use of fitting methods that take into account the interval-censored nature of propagule retention time data proved necessary for a correct estimation of the underlying probability distributions. If we take the example of the lognormal fit to interval upper-bound data, which is the most used fitting method, a difference of 0.27 in the location parameter μ (i.e., 1.3 h in median retention time) was observed in relation to the original parameter. If the vector flies at an average speed of 60 km/h, a common speed for waterfowl species , the difference in median dispersal distance (= 1.3 h × 60 km/h) would be 78 km, provided that the vector moves linearly until propagule retrieval. Even if actual vector movement distances are incorporated into dispersal distance estimations, considerable biases are also observed, mostly in the estimation of long distance dispersal (Table 1). The magnitude of these biases stress the necessity of using fitting methods that are able to account for the censored nature of propagule retention time data.
The two estimation methods based on cumulative distributions (CD-ML and CD-NLS) produced accurate estimations for lognormal, gamma and Weibull distributions and were remarkably robust against variations in data quality (sample size and sampling-time interval). The CD-NLS method requires more data points than the CD-ML method to be equally robust, as its estimation did not converge for distributions with a low variance (i.e., resulting from either a reduced retention time range or too large sampling time-intervals). We therefore recommend the CD-ML method, which fits the parameters to the censored data by maximum likelihood, as a general approach to characterize the probability distribution of propagule retention time. It can be implemented via the R package fitdistrplus  and other software packages such as MATLAB and SAS (this is not an exhaustive list).
The accuracy of estimations with the best method (CD-ML) was high enough to ensure very low deviations from the original distribution, as the maximum observed deviation in cumulative probability (compared to the original probability distribution) was only 0.05 (KS-statistic). Although distribution fittings using the interval mid-points also provided satisfactory results, estimated parameters were not as accurate as those using cumulative distributions. In particular, the variance parameter (σ) was generally overestimated, mostly at low sample sizes. The overestimation of this parameter might result in overestimated dispersal distances and, consequently, overestimated frequencies of long distance dispersal (as inferred from [4, 18]).
The robustness of the CD-ML method suggests that many hitherto obtained datasets on propagule retention time might be properly used in mechanistic models of propagule dispersal, even if the tail of the distribution is undersampled [e.g., 19]). Our results also suggest that the experimental conditions may and should be designed to optimize the accurate characterization of retention-time probability distributions by taking into account the tradeoff between sampling effort and measurement precision. Simulations suggested that (i) at least 500 propagules should be retrieved to obtain more reliable estimates of retention time, and (ii) sampling effort should ensure an accurate characterization of the time peak (i.e., mode) of propagule retrieval by choosing sampling time-intervals of shorter length than the peak retrieval. Although the sampling effort for the distribution tail can be more relaxed, adequate sampling time-intervals should also be used until the end.
Based on our comparative analysis, we recommend the use of the CD-ML method to fit parametric probability distributions to propagule retention-time data. Because propagule retention time is a key parameter in mechanistic models of passive dispersal [4, 18], an accurate parametric characterization of its probability distribution contributes to more reliable estimations of dispersal kernels and shadows. Given that many plants, invertebrates and microbes (including aquatic taxa) rely on passive dispersal, and that dispersal is a key determinant of biodiversity distribution patterns, the methodology presented in this study will also be useful for modeling population and community dynamics (e.g., meta-population and -community models), as well as species distributions (e.g., species distribution models; SDMs).
We assessed the performance of the five different procedures used to fit parametric probability distributions to “empirical” datasets by comparing the distributions obtained from such fits with the original distributions from which the “empirical” datasets were randomly sampled. Original distributions were aimed at representing the propagule retention time of a given vector species; hence, we obtained them from a study in which the gut retention time of seeds fed to several waterfowl species was measured and fitted to three types of probability distribution—lognormal, gamma and Weibull (Fig. 1) . These distributions are suited to characterize the distribution of propagule retention times, and although having a reduced number of parameters, their flexibility allows them to represent a broad variety of curve shapes [4, 33].
The general procedure was as follows. First, we generated the “empirical dataset” by drawing a random sample of the original distribution of propagule retention times and assigning the resulting values to predefined sampling time-intervals (thus simulating empirical sampling in real-world studies). We repeated this procedure 100 times for each original probability distribution to account for random variation. Second, we fitted a probability distribution (of the same type as the original one) to the empirical dataset, using the five procedures outlined above—i.e., fits to either the lower-bound, mid-interval or upper-bound values of the corresponding time interval, or fits to the cumulative distribution of empirical, upper-bound data. In the first three methods, interval bounds (either lower, mid or upper points) were considered to represent a continuous variable and the parameters of the fitted distributions were estimated by maximum likelihood (i.e., calculated according to probability density). For the methods using the empirical cumulative distribution, we estimated the parameters of fitted distributions either by maximum likelihood (method hereafter termed CD-ML), according to the procedure presented in Delignette-Muller and Dutang  (see [41, 42] for further details), or by non-linear least squares (method hereafter termed CD-NLS). All fittings were performed in R  using package fitdistrplus  for maximum likelihood estimation (function fitdist for the fittings using the time-interval bounds, and function fitdistcens for the CD-ML method), and the R base package for the CD-NLS method (function nls). We then assessed the fitting performance by comparing estimated and original distribution parameters (difference in value), and by estimating the Kolmogorov–Smirnov (KS) statistic using the package kolmin  in R . The KS-statistic was obtained by drawing a random sample of the fitted distribution (N = 500) and comparing it with the original distribution. It represents the maximum difference in cumulative probability between the reference and focal distributions, thus corresponding to a goodness-of-fit measure ranging from zero (i.e., 100 % accurate) to one.
Robustness of the different fitting methods
We assessed the robustness of the five fitting methods by simulating natural variation in propagule retention time (i.e., by varying the type and shape of original distributions) and different experimental designs commonly found in the literature, namely variation in sample size and in the length of sampling-time intervals. We applied the procedures described above to the sets of simulated data described below.
Variation in distribution type and shape
We assessed the robustness of the fitting method to variation in the probability distribution by using three distribution types (lognormal, gamma and Weibull) and 30 different sets of parameters (variation in parameter values) to generate the original distributions from which “empirical datasets” were randomly drawn. To obtain a representative set of parameter combinations for each distribution type, we applied a Latin Hypercube Sampling procedure to the range of parameter variation reported in Viana et al. , using the R package lhs .
Variation in sample size
We assessed the robustness of the fitting method to variation in sample size by varying the size of the random samples drawn from each original distribution, i.e., by simulating different numbers of retrieved propagules (ranging from N = 50 to N = 1500). We restricted this analysis to a single type of original distribution, and chose to use the lognormal distribution due to its wide use in studies describing gut retention time in different animal vectors [4, 33]. The lognormal distribution was defined with parameter values corresponding to the mean of the parameters’ range reported in Viana et al. . Sampled data for each simulation were assigned to sampling time-intervals corresponding to the lengths that provided the best performance (see Results; below we explain interval length variation).
Variation in the length of sampling time-intervals
We assessed the robustness of the fitting method to different sampling time-intervals by varying, either uniformly or asymmetrically, the length of the time intervals used to sample data from the original distribution. We used both regular intervals over the whole sampling period, using three different lengths (either 1, 2 or 4 h, throughout the whole range of 52 h), and variable interval lengths. The latter varied in length (i) around the distribution mode, defining intervals of 1, 2 or 4 h during the first 8 h followed in all three cases by intervals of 4 h throughout the remaining sampling period, (ii) in the tail of the distribution, defining intervals of 1 h up to 8 h followed by intervals of either 2, 4 or 8 h afterwards, or (iii) only in the last interval, defining intervals of 1 h until 8 h and 4 h until either 12, 24 or 36 h followed by a variable last sampling bout at the end of the sampling procedure (52 h). All these sampling schemes reproduce procedures used in published studies [e.g., 19, 24, 27, 37], though additional variation was introduced in some of them. We used the lognormal distribution as the original distribution and a sample size of 500 propagules.
Impact of fitting method on estimates of propagule dispersal kernels
To assess the bias produced by non-optimal fitting methods on various dispersal kernel properties, we compared the discrepancy in four dispersal kernel parameters (long-distance dispersal frequency, mean and median distance, and the 99th distance percentile) estimated using retention-time distributions fitted according to the five fitting methods described in the previous sections (only lognormal distributions were used). For this purpose, we used two examples [from 24, 37] in which the seed retention times of two aquatic plant species (P. pectinatus and S. lacustris) in the guts of a single waterfowl species (mallard Anas platyrhynchos) were measured using different sampling time-intervals (every 4 h for P. pectinatus versus every hour up to 4 h, every 2 h up to 8 h, and every 4 h afterwards for S. lacustris). Dispersal kernels were estimated using a realistic distribution of vector movement distances, based on waterfowl banding data (data available in ). For each of the four dispersal kernel parameters, we calculated the relative difference (in percentage) between the value obtained using the optimal method (CD-ML; see results) and each of all other fitting methods.
Availability of data and materials
The datasets supporting the conclusions of this article are available in the Dryad Digital Repository, http://datadryad.org/resource/doi:10.5061/dryad.619gd.
DSV carried out the statistical analysis and wrote the manuscript. DSV, LS and JF conceived of the study, participated in its design and coordination, and helped to draft the manuscript. All authors read and approved the final manuscript.
This study was supported by project P09-RNM-4744 from Junta de Andalucía. DSV was supported by project RECUPERA 2020, Hito 1.1.1, cofinanced by the European Social Fund (ESF). LS was supported by project GENSABINA, ref. 476/2011, funded by the OAPN (Spanish Ministry of Environment).
The authors declare that they have no competing interests.
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- Cousens RD, Hill J, French K, Bishop ID. Towards better prediction of seed dispersal by animals. Funct Ecol. 2010;24:1163–70.View ArticleGoogle Scholar
- Nathan R, Muller-Landau HC. Spatial patterns of seed dispersal, their determinants and consequences for recruitment. Trends Ecol Evol. 2000;15:278–85.View ArticlePubMedGoogle Scholar
- Nathan R, Schurr FM, Spiegel O, Steinitz O, Trakhtenbrot A, Tsoar A. Mechanisms of long-distance seed dispersal. Trends Ecol Evol. 2008;23:638–47.View ArticlePubMedGoogle Scholar
- Viana DS, Santamaría L, Michot TC, Figuerola J. Allometric scaling of long-distance seed dispersal by migratory birds. Am Nat. 2013;181:649–62.View ArticlePubMedGoogle Scholar
- Will H, Tackenberg O. A mechanistic simulation model of seed dispersal by animals. J Ecol. 2008;96:1011–22.View ArticleGoogle Scholar
- Bilton DT, Freeland JR, Okamura B. Dispersal in freshwater invertebrates. Annu Rev Ecol Syst. 2001;32:159–81.View ArticleGoogle Scholar
- Figuerola J, Green AJ. Dispersal of aquatic organisms by waterbirds: a review of past research and priorities for future studies. Freshwat Biol. 2002;47:483–94.View ArticleGoogle Scholar
- Howe HF, Smallwood J. Ecology of seed dispersal. Annu Rev Ecol Syst. 1982;13:201–28.View ArticleGoogle Scholar
- Levin SA, Muller-Landau HC, Nathan R, Chave J. The ecology and evolution of seed dispersal: a theoretical perspective. Annu Rev Ecol Evol Syst. 2003;34:575–604.View ArticleGoogle Scholar
- Van Leeuwen CHA, van der Velde G, van Groenendael JM, Klaassen M. Gut travellers: internal dispersal of aquatic organisms by waterfowl. J Biogeogr. 2012;39:2031–40.View ArticleGoogle Scholar
- Costa JM, Ramos JA, da Silva LP, Timoteo S, Araújo PM, Felgueiras MS, Rosa A, Matos C, Encarnação P, Tenreiro PQ, et al. Endozoochory largely outweighs epizoochory in migrating passerines. J Avian Biol. 2014;45:59–64.View ArticleGoogle Scholar
- Herrera CM. Seed dispersal by vertebrates. In: Herrera CM, Pellmyr O, editors. Plant-animal interactions: an evolutionary approach. Oxford: Blackwell; 2002. p. 185–208.Google Scholar
- Jacobson B, Peres-Neto P. Quantifying and disentangling dispersal in metacommunities: how close have we come? How far is there to go? Landscape Ecol. 2010;25:495–507.View ArticleGoogle Scholar
- Clark JS, Fastie C, Hurtt G, Jackson ST, Johnson C, King GA, Lewis M, Lynch J, Pacala S, Prentice C, et al. Reid’s paradox of rapid plant migration. Bioscience. 1998;48:13–24.View ArticleGoogle Scholar
- Gillespie RG, Baldwin BG, Waters JM, Fraser CI, Nikula R, Roderick GK. Long-distance dispersal: a framework for hypothesis testing. Trends Ecol Evol. 2012;27:47–56.View ArticlePubMedGoogle Scholar
- Engler R, Hordijk W, Guisan A. The MIGCLIM R package—seamless integration of dispersal constraints into projections of species distribution models. Ecography. 2012;35:872–8.View ArticleGoogle Scholar
- Nobis MP, Normand S. KISSMig—a simple model for R to account for limited migration in analyses of species distributions. Ecography. 2014;37:1282–7.View ArticleGoogle Scholar
- Guttal V, Bartumeus F, Hartvigsen G, Nevai AL. Retention time variability as a mechanism for animal mediated long-distance dispersal. PLoS One. 2011;6:e28447.View ArticlePubMed CentralPubMedGoogle Scholar
- Soons MB, van der Vlugt C, van Lith B, Heil GW, Klaassen M. Small seed size increases the potential for dispersal of wetland plants by ducks. J Ecol. 2008;96:619–27.View ArticleGoogle Scholar
- Sorensen AE. Seed dispersal by adhesion. Annu Rev Ecol Syst. 1986;17:443–63.View ArticleGoogle Scholar
- Charalambidou I, Ketelaars HAM, Santamaría L. Endozoochory by ducks: influence of developmental stage of Bythotrephes diapause eggs on dispersal probability. Divers Distrib. 2003;9:367–74.View ArticleGoogle Scholar
- Charalambidou I, Santamaria L, Langevoord O. Effect of ingestion by five avian dispersers on the retention time, retrieval and germination of Ruppia maritima seeds. Funct Ecol. 2003;17:747–53.View ArticleGoogle Scholar
- Karasov WH. Digestion in birds: chemical and physiological determinants and ecological implications. Stud Avian Biol. 1990;13:391–415.Google Scholar
- Charalambidou I, Santamaria L, Jansen C, Nolet BA. Digestive plasticity in Mallard ducks modulates dispersal probabilities of aquatic plants and crustaceans. Funct Ecol. 2005;19:513–9.View ArticleGoogle Scholar
- Figuerola J, Green AJ. Effects of premigratory fasting on the potential for long distance dispersal of seeds by waterfowl: an experiment with marbled teal. Revue D Ecologie-La Terre Et La Vie. 2005;60:283–7.Google Scholar
- Kleyheeg E, van Leeuwen CHA, Morison MA, Nolet BA, Soons MB. Bird-mediated seed dispersal: reduced digestive efficiency in active birds modulates the dispersal capacity of plant seeds. Oikos. 2014;124(7):899–907.View ArticleGoogle Scholar
- Van Leeuwen CHA, Tollenaar ML, Klaassen M. Vector activity and propagule size affect dispersal potential by vertebrates. Oecologia. 2012;170:101–9.View ArticlePubMed CentralPubMedGoogle Scholar
- Westcott DA, Bentrupperbaumer J, Bradford MG, McKeown A. Incorporating patterns of disperser behaviour into models of seed dispersal and its effects on estimated dispersal curves. Oecologia. 2005;146:57–67.View ArticlePubMedGoogle Scholar
- Fischer SF, Poschlod P, Beinlich B. Experimental studies on the dispersal of plants and animals on sheep in calcareous grasslands. J Appl Ecol. 1996;33:1206–22.View ArticleGoogle Scholar
- Manzano P, Malo JE. Extreme long-distance seed dispersal via sheep. Front Ecol Environ. 2006;4:244–8.View ArticleGoogle Scholar
- Tackenberg O, Römermann C, Thompson K, Poschlod P. What does diaspore morphology tell us about external animal dispersal? Evidence from standardized experiments measuring seed retention on animal-coats. Basic Appl Ecol. 2006;7:45–58.View ArticleGoogle Scholar
- Kays R, Jansen PA, Knecht EMH, Vohwinkel R, Wikelski M. The effect of feeding time on dispersal of Virola seeds by toucans determined from GPS tracking and accelerometers. Acta Oecol. 2011;37:625–31.View ArticleGoogle Scholar
- Rawsthorne J, Roshier DA, Murphy SR. A simple parametric method for reducing sample sizes in gut passage time trials. Ecology. 2009;90:2328–31.View ArticlePubMedGoogle Scholar
- Rodríguez-Pérez J, Larrinaga AR, Santamaría L. Effects of frugivore preferences and habitat heterogeneity on seed rain: a multi-scale analysis. PLoS One. 2012;7:e33246.View ArticlePubMed CentralPubMedGoogle Scholar
- Santamaría L, Rodriguez-Perez J, Larrinaga AR, Pias B. Predicting spatial patterns of plant recruitment using animal-displacement kernels. PLoS One. 2007;2(e1008):1001–9.Google Scholar
- Uriarte M, Anciães M, da Silva MTB, Rubim P, Johnson E, Bruna EM. Disentangling the drivers of reduced long-distance seed dispersal by birds in an experimentally fragmented landscape. Ecology. 2011;92:924–37.View ArticlePubMedGoogle Scholar
- Figuerola J, Charalambidou I, Santamaria L, Green A. Internal dispersal of seeds by waterfowl: effect of seed size on gut passage time and germination patterns. Naturwissenschaften. 2010;97:555–65.View ArticlePubMedGoogle Scholar
- Alerstam T, Rosén M, Bäckman J, Ericson PGP, Hellgren O. Flight speeds among bird species: allometric and phylogenetic effects. PLoS Biol. 2007;5:e197.View ArticlePubMed CentralPubMedGoogle Scholar
- Delignette-Muller ML, Pouillot qR, Denis J-B, Dutang C. Fitdistrplus: help to fit of a parametric distribution to non-censored or censored data. R package version 0.10. http://www.CRANR-projectorg/package=fitdistrplus. 2014.
- Delignette-Muller ML, Dutang C. Fitdistrplus: an R package for fitting distributions. J Stat Softw. 2015;64(4):1–34.View ArticleGoogle Scholar
- Helsel DR. Nondetects and data analysis. Statistics for censored environmental data. 1st ed. Wiley: Interscience; 2005.Google Scholar
- Klein JP, Moeschberger ML. Survival analysis: techniques for censored and truncated data. 2nd ed. Springer: Science & Business Media. 2003.Google Scholar
- R Development Core Team. A language and environment for statistical computing. Vienna: R Foundation for Statistical Computing. ISBN 3-900051-07-0. URL http://www.R-projectorg. 2015.
- Carvalho L. kolmim: An improved evaluation of Kolmogorov’s distribution. R package version 0.2. http://www.CRANR-projectorg/package=kolmim. 2014.
- Carnell R. lhs: Latin Hypercube Samples. R package version 0.10. http://www.CRANR-projectorg/package=lhs. 2012.