The Probability of a Gene Tree Topology within a Phylogenetic Network with Applications to Hybridization Detection
Published in the journal:
. PLoS Genet 8(4): e32767. doi:10.1371/journal.pgen.1002660
Category:
Research Article
doi: 10.1371/journal.pgen.1002660
Summary
Gene tree topologies have proven a powerful data source for various tasks, including species tree inference and species delimitation. Consequently, methods for computing probabilities of gene trees within species trees have been developed and widely used in probabilistic inference frameworks. All these methods assume an underlying multispecies coalescent model. However, when reticulate evolutionary events such as hybridization occur, these methods are inadequate, as they do not account for such events. Methods that account for both hybridization and deep coalescence in computing the probability of a gene tree topology currently exist for very limited cases. However, no such methods exist for general cases, owing primarily to the fact that it is currently unknown how to compute the probability of a gene tree topology within the branches of a phylogenetic network. Here we present a novel method for computing the probability of gene tree topologies on phylogenetic networks and demonstrate its application to the inference of hybridization in the presence of incomplete lineage sorting. We reanalyze a Saccharomyces species data set for which multiple analyses had converged on a species tree candidate. Using our method, though, we show that an evolutionary hypothesis involving hybridization in this group has better support than one of strict divergence. A similar reanalysis on a group of three Drosophila species shows that the data is consistent with hybridization. Further, using extensive simulation studies, we demonstrate the power of gene tree topologies at obtaining accurate estimates of branch lengths and hybridization probabilities of a given phylogenetic network. Finally, we discuss identifiability issues with detecting hybridization, particularly in cases that involve extinction or incomplete sampling of taxa.
Introduction
A molecular systematics paradigm that views molecular sequences as the characters of gene trees, and gene trees as characters of the species tree [1] is being increasingly adopted in the postgenomic era [2], [3]. Several models of evolution for the former type of characters have been devised [4], while the coalescent has been the main model of the latter type of characters [5], [6]. However, hybridization, a process that is believed to play an important role in the speciation and evolutionary innovations of several groups of plant and animal species [7], [8], results in reticulate (species) evolutionary histories that are best modeled using a phylogenetic network [9], [10]. Further, as hybridization may occur between closely related species, incongruence among gene trees may also be partly due to deep coalescence, and distinguishing between the two factors is hard under these conditions [11]. Therefore, to enable a more general application of the new paradigm, a phylogenetic network model that allows simultaneously for deep coalescence events as well as hybridization is needed [12]. This model can be devised by extending the coalescent model to allow for computing gene tree probabilities in the presence of hybridization. In this paper we focus on gene tree topologies and analyze the signal they contain for detecting hybridization in the presence of deep coalescence.
Applications of probabilities of gene tree topologies given species trees include determining statistical consistency (or inconsistency) of topologybased methods for inferring species trees 13–15, testing the multispecies coalescent model [13], [16], determining identifiability of species trees using linear invariants of functions of gene tree topology probabilities [17], [18], delimiting species [19], designing simulation studies for species tree inference methods [20]–[22], and inferring species trees [23], [24]. We expect that similar applications may be useful for probabilities of gene tree topologies given species networks. In particular, it will be useful to be able to evaluate the performance of methods that infer species trees in the presence of hybridization as well as the performance of methods for inferring species networks. Knowing the distribution of gene tree topologies could also be useful for estimating the probability that two gene trees have the same topology, a quantity that is used in constructing the prior which models gene tree discordance in BUCKy [25], a program that is often used to estimate species trees or concordance trees.
A method for computing the probability mass function of gene tree topologies in the absence of hybridization (i.e., under the multispecies coalescent model is assumed) is given by Degnan and Salter [26]. However, to handle hybridization and deep coalescence simultaneously, this method has to be extended to allow for reticulate species evolutionary histories.
Indeed, attempts have been made recently for this very task [27]–[30], all of which have focused on very limited special cases where the phylogenetic network topology is known and contains one or two hybridization events, and a single allele sampled per species. However, a general formula for the probability of a gene tree topology given a general (any number of taxa, hybridizations, gene trees, and/or alleles) phylogenetic network has remained elusive.
A binary phylogenetic network topology contains two types of nodes: tree nodes, each of which has exactly one parent (except for the root, which has zero parents), and reticulation nodes, each of which has exactly two parents. The edge incident into a tree node is called tree edge, and the edges incident into a reticulation node are called reticulation edges. In our context, we associate with a phylogenetic network a vector of branch lengths (in units of generations, where is the effective population size in that branch) and a vector of hybridization probabilities (which indicates for each allele in a hybrid population its probability of inheritance from each of the two parent populations); see Text S1 for formal definition. The gene tree topology can be viewed as a random variable with probability mass function . In this paper, we solve the aforementioned open problem by reporting on a novel method for computing the probability of a gene tree topology given a phylogenetic network, .
We illustrate the use of gene tree topology probabilities to estimate the values of species network parameters using the likelihood of the gene tree topologies. This application allows for disentangling hybridization and deep coalescence when analyzing a set of incongruent gene trees, as both events can give rise to similar incongruence patterns. Given a collection of gene tree topologies, one per locus, in a set of sampled loci, the likelihood function is given by(1)This formulation provides a framework for estimating the parameters and of an evolutionary history hypothesis , given a collection of gene trees . Estimates of 0 or 1 for the entries in the vector reflect the absence of evidence for hybridization based on the gene tree topology distribution.
As gene tree topologies are estimated from sequence data, there is often uncertainty about them. In our method, we account for that in two ways: (1) by considering a set of gene tree topology candidates, along with their associated probabilities (produced, for example, by a Bayesian analysis), and (2) by considering for each locus the strict consensus of all optimal tree topologies computed for that locus (produced, for example, by a maximum parsimony analysis).
Finally, to account for model complexity, we employ a simple technique based on three information criteria, AIC [31], AICc [32] and BIC [33]. While these criteria have their shortcomings for model selection, the question of how to account for phylogenetic network complexity is still wide open and no methods exist for addressing it systematically [10].
We have implemented our method in the publicly available software package PhyloNet [34] and demonstrated its broad utilities in three domains. First, we reanalyze a Saccharomyces data set and a Drosophila data set, and find support for hybridization in both data sets. Second, we show the identifiability of the parameter values of certain reticulate evolutionary histories. Third, we highlight and discuss the lack of identifiability of the parameters in other scenarios that involve extinctions.
Materials and Methods
We begin by reviewing Degnan and Salter's method for computing the probability gene tree topologies on species trees, and then describe our novel extension to the case of species networks.
The probability of a gene tree topology within a species tree
Degnan and Salter [26] gave the mass probability function of a gene tree topology for a given species tree with topology and vector of branch lengths as(2)which is taken over coalescent histories from the set of all coalescent histories . The product is taken over all internal branches of the species tree. The term is the probability that lineages coalesce into lineages on branch whose length is . And the terms and represents the probability that the coalescent events agree with the gene tree topology. In particular, is the number of ways that coalescent events can occur consistently with the gene tree and is the number of sequences of coalescences that give the number of coalescent events specified by . However, this equation assumes that is a tree and as such is inapplicable to reticulate evolutionary histories. Recently, this equation was adapted to very special cases of species phylogenies with hybridization [28]–[30]. However, none of these adaptations is general enough to allow for multiple hybridizations, multiple alleles per species, or arbitrary divergence patterns following hybridization. We present a novel approach for generalizing this equation to handle hybridization. Our approach is general enough in that it allows for computing gene tree probabilities on any binary phylogenetic network topology, thus overcoming limitations of recent works.
The probability of a gene tree topology within a species network
Our approach for computing the probability of a gene tree given a species network has three steps. First, is converted into a multilabeled (MUL) tree (a tree whose leaves are not uniquely labeled by a set of taxa; see Text S1); second, the alleles at the tips of are mapped in every valid way to the tips of ; and, finally, the probability of is computed as the sum, over all valid allele mappings, of probabilities of given (see Figure 1).
Step 1: Converting the phylogenetic network to MUL tree
Let be a phylogenetic network on set of species, and with branch lengths vector and hybridization probabilities vector . The conversion of into a MUL tree is done as follows. Traversing the network from the leaves towards the root, every time a reticulation node is encountered, the two reticulation edges incident into it are removed, an additional copy of the subtree rooted at 's child is created, one copy is attached as child of one of 's original parents, and the other is attached as a child of 's other original parent. For example, in Figure 1, traversing the phylogenetic network from the leaves towards the root, the reticulation node is encountered, two copies of the subtree rooted at its child (i.e., the most recent common ancestor of and ) are created, and one is attached as a child of 's parent , and the other is attached as a child of 's parent , resulting in the MUL tree shown in the figure. In order to keep track of which branches in the MUL tree originated from the same branch in the phylogenetic network, we build during the conversion a mapping from the set of the MUL tree branches to the set of the phylogenetic network branches, such that if branch in the MUL tree corresponds to branch in the phylogenetic network. We make use of in two ways. The first is in transferring the branch lengths and hybridization probabilities from to the resulting MUL tree , as illustrated briefly in Figure 1 and in more details in Text S1, and the second use is for computing the probabilities of gene trees, as becomes clearer below. Upon completion of this step of converting the phylogenetic network , its branch lengths and hybridization probabilities , the result is a MUL tree along with its branch lengths , hybridization probabilities , and the branch mapping . The full description of the procedure NetworkToMULTree for achieving this conversion is given in Text S1.
Step 2: Mapping the alleles to the leaves of the MUL tree
In computing the probability of a gene tree given a species phylogeny (tree or network), all the alleles sampled from species are mapped to the single leaf labeled in the species phylogeny. However, unless the species phylogeny does not have any reticulation nodes, the resulting MUL tree contains leaf sets that are labeled by the same species . For example, in Figure 1, the MUL tree has two leaves labeled and two leaves labeled . In this case, it is important to map the alleles systematically to the leaves of the MUL tree so as to cover exactly all the coalescence patterns that would arise had the alleles been mapped to the phylogenetic network.
We denote by the set of leaf nodes in that are labeled by species . For example, for the MUL tree in Figure 1 is the set of the two leaves labeled by . Now, consider a locus . We denote by (for ) the set of alleles sampled from species for locus , and by the size of this set (i.e., ). In the example of Figure 1, two alleles were sampled from species ; hence, and . A valid allele mapping is a function such that if , and , then . In other words, maps an allele from species to a leaf in the MUL tree labeled by . Let denote the set of all such valid allele mappings ; in Figure 1, .
Step 3: Computing the probability of a gene tree on the MUL tree
Once the phylogenetic network is converted into MUL tree and the set of all valid allele mappings is produced (a straightforward computational task, yet results in a number of valid allele mappings that is exponential in a combination of the number of alleles sampled and the number of reticulation nodes), the probability of observing gene tree topology is found by summing the probability of given the MUL tree over all possible allele mappings. Then, the probability of observing gene tree topology is found by summing over all possible allele mappings:(3)In this equation, the term accounts for all coalescent histories of a given mapping, which, when combined with the summation over all valid allele mappings, accounts for all coalescent histories within the branches of a phylogenetic network. Finally, the likelihood for a collection of gene trees is the product of the individual gene tree probabilities. This formulation naturally gives rise to a likelihood setup for estimating the parameters of a reticulate evolutionary history from a collection of gene trees described by their topologies.
To complete our framework, we now provide a formula for , which is the probability of a gene tree given a MUL tree and a valid allele mapping. Special attention needs to be paid to sets of branches in the MUL tree that correspond to single branches in the phylogenetic network, since coalescence events within these branches are not independent. Let us illustrate this issue using valid allele mapping and the MUL tree in Figure 1. Under this mapping, each of the two alleles sampled from species B is mapped to a different B leaf in . Tracing these two alleles independently from the two B leaves implicitly indicates that tracing the evolution of these two alleles in the phylogenetic network, no coalescence event should occur within time on the branch incident into leaf B in the network. Additionally, each branch in the MUL tree may have a hybridization probability associated with it that is neither 0 nor 1, and must be accounted for in computing the probabilities. Accounting for these two cases gives rise to(4)where the terms are symbolic quantities, that do not individually evaluate to any value. Instead, they play a role in simultaneously computing the probability along pairs of branches in the MUL tree that share a single source branch in the phylogenetic network. More formally, let be a branch in such that is a reticulation node. Given the mapping from the branches of to the branches of , the preimage (or, inverse image) is the set of all branches in that map to under . That is, , where is the set of 's branches. Then, we define(5)This equation states that the number of lineages that enters (working backward in time) branch in the phylogenetic network equals the sum of the numbers of lineages that enter all branches of the MUL tree that map to branch . The number of lineages that exists branch is defined similarly. In Figure 1, the number of lineages that enters branch in the phylogenetic network equals the sum of the number of lineages that enter branch and the number of lineages that enter branch in the MUL tree.
Then, we use the following equation to evaluate the probability in Equation (4):(6)where is computed using the formula in [26], with and as parameters. In the example of branches , and that we just illustrated, Equation (6) states that evaluates toThe term gives the probability that lineages coalesce into lineages within time . The termcorresponds to the quantity in [26]. Finally, the termis the number of restrictions for the ordering of coalescent events within branch .
Accounting for uncertainty in gene tree topologies
Thus far, we have assumed that we have an accurate, fully resolved gene tree for each locus. However, in practice, gene tree topologies are inferred from sequence data and, as such, there is uncertainty about them. In Bayesian inference, this uncertainty is reflected by a posterior distribution of gene tree topologies. In a parsimony analysis, several equally optimal trees are computed. We propose here a way for incorporating this uncertainty into the framework above. Assume we have loci under analysis, and for each locus , a Bayesian analysis of the sequence alignment returns a set of gene trees , along with their associated posterior probabilities (). Now, let be the set of all distinct tree topologies computed on all loci, and for each let be the sum of posterior probabilities associated with all gene trees computed over all loci whose topology is . Thus, and . Then, we replace Eq. (1) by(7)We note that if or for each and , then Eq. (7) is equivalent to Eq. (1), and both are multinomial likelihoods. This multinomial approach has also been used elsewhere for both species networks under simple hybridization scenarios [28] and species trees [24]. We additionally allow the terms to be between 0 and 1 (and therefore to be noninteger values) in order to reflect uncertainty in the estimated gene trees.
In the case where a maximum parsimony analysis is conducted to infer gene trees on the individual loci, a different treatment is necessary, since for each locus, all inferred trees are equally optimal. For locus , let be the strict consensus of all optimal gene tree topologies found. Then, Eq. (1) becomes(8)where is the set of all binary refinements of gene tree topology .
Results
Support for hybridization in yeast
Using our method to compute the likelihood function given by Eq. (1), we reanalyzed the yeast data set of [35], which consists of 106 loci, each with a single allele sampled from seven Saccharomyces species S. cerevisiae (Scer), S. paradoxus (Spar), S. mikatae (Smik), S. kudriavzevii (Skud), S. bayanus (Sbay), S. castellii (Scas), S. kluyveri (Sklu), and the outgroup fungus Candida albicans (Calb). Given that there is no indication of coalescences deeper than the MRCA of Scer, Spar, Smik, Skud, and Sbay [36], we focused only on the evolutionary history of these five species (see Text S1). We inferred gene trees using Bayesian inference in MrBayes [37] and using maximum parsimony in PAUP* [38] (see Text S1 for settings).
The species tree that has been reported for these five species, based on the 106 loci, is shown in Figure 2A [35]. Further, additional studies inferred the tree in Figure 2B as a very close candidate for giving rise to the 106 gene trees, under the coalescent model [36], [39]. Notice that the difference between the two trees is the placement of Skud, which flags hybridization as a possibility. Indeed, the phylogenetic network topologies in Figure 2C and 2D have been proposed as an alternative evolutionary history, under the stochastic framework of [40], as well as the parsimony framework of [30].
Using the 106 gene trees, we estimated the times , , , and for the six phylogenies in Figure 2 that maximize the likelihood function (we used a grid search of values between 0.05 and 4, with step length of 0.05 for branch lengths, and values between 0 and 1 with step length of 0.01 for ). Table 1 lists the values of the parameters computed using Eq. (7) on the gene trees inferred by MrBayes and Table 2 lists the values of the parameters computed using Eq. (8) on the gene trees inferred by PAUP*, as well as the values of three information criteria, AIC [31], AICc [32] and BIC [33], in order to account for the number of parameters and allow for model selection.
Out of the 106 gene trees (using either of the two inference methods), roughly 100 trees placed Scer and Spar as sister taxa, which potentially reflects the lack of deep coalescence involving this clade (and is reflected by the relatively large values estimated). Roughly 25% of the gene trees did not show monophyly of the group Scer, Spar, and Smik, thus indicating a mild level of deep coalescence involving these three species (and reflected by the relatively small values estimated). However, a large proportion of the 106 gene trees indicated incongruence involving Skud; see . This pattern is reflected by the very low estimates of the time on the two phylogenetic trees in Figure 2. On the other hand, analysis under the phylogenetic network models of Figure 2C and 2D indicates a larger divergence time, with substantial extent of hybridization. These latter hypotheses naturally result in a better likelihood score. When accounting for model complexity, all three information criteria indicated that these two phylogenetic network models with extensive hybridization and larger divergence time between Sbay and the ( Smik,( Scer,Spar)) clade provide better fit for the data. Further, while both networks produced identical hybridization probabilities, the network in Figure 2D had much lower values of the information criteria than those of the network in Figure 2E. The networks in Figure 2E and 2F have lower support (under all measures) than the other four phylogenies. In summary, our analysis gives higher support for the hypothesis of extensive hybridization, a low degree of deep coalescence, and long branch lengths than to the hypothesis of a species tree with short branches and extensive deep coalescence. It is worth mentioning that while the three networks in Figure 2C–2E were reported as equally optimal under a parsimonious reconciliation [36], our new framework can distinguish among the three, and identifies the network in Figure 2D as best, followed by the one in Figure 2C (the network of Figure 2E is found to be a worse fit than either of the two species tree candidates).
Support for hybridization in Drosophila
We reanalyzed the threespecies Drosophila data set of [41], which includes D. melanogaster ( Dmel), D. yakuba ( Dyak), and D. erecta ( Dere).
The data set consisted of loci supporting the three possible gene tree topologies as follows:

gene tree is supported by () loci;

gene tree is supported by () loci; and,

gene tree is supported by () loci.
For a species tree with three species and one individual sampled per species, the multispecies coalescent predicts that the two gene trees with topologies different from that of the species tree each occur with probability , where is the length of the one internal branch in coalescent units [42]. Two important predictions under the coalescent are therefore that the two nonmatching gene trees are expected to be tied in frequency and that both occur less than of the time, with the matching gene tree topology occurring more than of the time. This tie in the expected frequency of nonmatching gene trees is observed in some threetaxon data sets, but not in others, including the Drosophila data set.
Although this deviation from symmetry can be explained by a model of population subdivision, where the subdivision must occur in the internal branch as well as the population ancestral to all three species [43], the asymmetry can also be explained by the simplest hybridization network on three species with just one hybridization parameter (Figure 3).
We considered six candidates for the species phylogeny: three with no hybridization, and three with hybridizations involving different pairs of species (see Figure 3). For the three phylogenetic trees, we estimated the time that maximizes the probability of observing all gene trees, and for the three phylogenetic networks, we additionally estimated the hybridization probability .
The results in Table 3 show that of the three phylogenetic trees, the one in Figure 3A provides the best fit of the data, which is in agreement with the analysis in [41]. In fact, the value of we estimated on the other two trees was the lowest value we used in the estimation procedure. Clearly, this value can be arbitrarily small for these two trees, since the unresolved phylogeny ( Dmel, Dere, Dyak) fits the data better.
Among the three network candidates, the one in Figure 3D has the best fit of the data. This network, with a value of , indicates that of the alleles sampled from Dere shared a common ancestor first with alleles from Dyak (reflecting the tree in Figure 3A), while of the alleles from Dere shared a common ancestor first with alleles from Dmel (reflecting the tree in Figure 3B). Indeed, this network is the smallest network (in terms of the number of reticulation nodes) that reconciles both trees. Further, the change in AIC for this network is , indicating a much better fit than the best tree (Figure 3A). As noted previously [43], a square test will also strongly reject the hypothesis that the species relationships are treelike with random mating.
This threetaxon example can be analyzed analytically. Fitting a hybridization parameter allows a perfect fit to any observed frequencies of gene tree topologies for three species for one of the three networks in Figure 3. We let , , and represent the probabilities of topologies (Dmel,( Dere, Dyak)), ((Dmel, Dere), Dyak), and ((Dmel, Dyak), Dere) under the network in Figure 3D. Then
This system has the unique solution(9)for and (either at least one of the gene tree probabilities is less than if since they sum to 1.0; or if they are all exactly 1/3, then a star tree with and any exactly fits the data). Thus we can estimate and using the observed and in equation (9), and this also maximizes the likelihood.
Identifiability of hybridization using gene tree topologies: A simulation study
For the simulated data, we evolved gene trees within the branches of phylogenetic networks, while varying branch lengths and hybridization probabilities, and investigated two questions: (1) how much data (gene trees) is needed to obtain accurate inference of the parameters (branch lengths and/or hybridization probabilities)? (2) are the parameters always identifiable? To answer these two questions, we investigated six different phylogenetic network topologies that involved single reticulation scenario, two reticulation scenarios (dependent and independent), and cases with extinctions involving the species that hybridize (see Text S1).
Our results show that both hybridization probabilities and branch lengths can be estimated with very high accuracy provided that no extinction events were involved in the parents of hybrid populations (see Text S1). Further, this accuracy can be achieved even when using the smallest number of gene trees we used in our study, which is 10. Under these settings, estimates using our framework seemed to converge quickly to the true values.
We also investigated the performance of the method, as well as identifiability issues when phylogenetic signal from at least one of the species involved in the hybridization is completely lost. Figure 4 shows the results for one such scenario (see Text S1 for another scenario that involves the loss of phylogenetic signal from both species involved in the hybridization).
Panels Figure 4B–4D show that when the true values of and are assumed to be known in the estimation procedure (the value of is irrelevant in the case when a single allele is sampled per species), the estimates of the hybridization probabilities converge to the true values. However, unlike the cases that did not involved extinctions, a larger number of gene trees is now required to obtain an accurate estimate (while there are only three possible gene tree topologies, a large number of gene trees need be sampled in order for the three topologies' frequencies to be informative). The time intervals of coalescent units amount to a large extent of deep coalescence events, which blurs the phylogenetic signal, and results in slight over or underestimation of the hybridization probabilities (Text S1 shows the results for the time interval with ).
If the topology of the network in Figure 4A is assumed to be known, but both the branch lengths and hybridization probabilities are to be estimated, then these parameters are unidentifiable; that is, two different pairs of vectors of branch lengths and hybridization probabilities can be found to explain the observed data with exactly the same probability (see Text S1). If at least two alleles are sampled from species B, then the parameter values become identifiable; however, an extremely large, and potentially infeasible, number of gene trees need to be sampled to uniquely identify the parameter values in practice (see Text S1).
Furthermore, in the special case where , a phylogenetic tree, with appropriate branch lengths can be found, to fit the data exactly with the same probability that the phylogenetic network would. Let be the branch lengths vector with , , and , and let be the hybridization probabilities vector with . Now, consider the phylogenetic tree in Figure 4E. Then, if we set as a function of , , and , using , then, for any gene tree . The values of are shown in Figure 4F–4H. These results show that as increases, the value of becomes unaffected by , and that increasing proportionally to the increase in always maintains identical probabilities of gene trees under both species phylogenies (see Text S1).
Our method for computing the probability of gene trees under hybridization and deep coalescence allows for analyzing data sets with arbitrary complexity of evolutionary histories in terms of the hybridization scenarios. When parameters are identifiable, our method estimates their values with high accuracy from a relatively small number of loci. Further, our method can be used to show lack of identifiability of model parameters for other cases. Our method supports a hypothesis of larger divergence time coupled with hybridization over short divergence times (with extensive deep coalescence) in a yeast data set. Finally, for a large Drosophila data set, our method indicated no hybridization based on the sampled loci.
Discussion
Using coalescence times versus topologies to infer species networks
We have focused on calculating probabilities of gene tree topologies and using these probabilities to infer species networks. In addition, the joint density of the coalescence times and topology in the gene trees could be used to infer species networks. Indeed, this approach has been used for networks where reticulation nodes have one descendant which is an extant species [29], using the density for coalescence times derived by Rannala and Yang [44]. This approach is computationally faster than computing gene tree topology probabilities because it is not necessary to sum over a large number of coalescent histories. To compute this joint density, each gene sampled can potentially have to trace through up to possible paths through the network, where is the number of hybridization events ancestral to the sampled gene from species , and the density will take the form of a sum over possible paths through the network. (In contrast, computing the probability of a topology will require mappings of alleles to the MULtree, and each gene topology calculation will require summing over coalescent histories.) This joint density for the gene trees with coalescence times could then be used in either maximum likelihood or Bayesian frameworks to infer the species network.
An important advantage of using coalescence times is that certain networks might be identifiable using coalescence times when probabilities of topologies might not identify the network. In the example of Figure 3A, although the gene tree topology probabilities can be obtained by a tree, the distribution of the coalescence times between lineages sampled from B and C is a mixture of three shifted exponential distributions if , but a mixture of two shifted exponential distributions if . For example, if , and are known but and are unkown, then the likelihood of observing a coalescence between a B and C lineage for times slightly greater will be very low if , and much higher for , thus making it possible to test whether when coalescence times are used.
Another identifiability issue is that both population subdivision and hybridization can lead to the asymmetry in gene tree topology probabilities in the 3taxon case such as observed in the Drosophila example discussed earlier, where the two least frequently observed topologies are not tied in frequency. Either population subdivision, with a parameter describing the probability that the two most closely related species fail to coalesce in the ancestral population due to population structure, or hybridization can fit the data for the gene tree topologies. However, the two models could imply different distributions on coalescence times, which might therefore be useful in distinguishing the models. We note that identifiability in the case of three species with one individual per species might be especially limited due to the small number of gene tree topology probabilities that can be used to estimate parameters. In the case of identifying rooted species trees from unrooted gene trees with one lineage per species, for example, identifiability is achieved only with 5 or more species [17].
We consider it desirable to develop many methods for inferring species trees and species networks so that their properties and performances can be compared. In the case of species tree inference, there are advantages and disadvantages to using topologybased methods versus methods that include branch lengths, and in using likelihood versus Bayesian methods. We expect that many of these strengths and weaknesses may carry over to the case of inferring networks. For moderately sized data sets, Bayesian methods that model branch lengths and uncertainty in the gene trees such as BEST [45] and *BEAST [46] often have the best performance [47]. However, these methods require estimating the joint posterior distribution of the species tree and gene trees and therefore are difficult to implement for large numbers of loci. Maximizing the likelihood of the gene trees and their coalescent times (but without accounting for uncertainty in the gene trees), as in STEM [48], is fast and has very good performance on known gene trees but seems to be very sensitive to the assumption that branch lengths are estimated correctly [24], [49]. Maximizing the likelihood of the species tree using only gene tree topologies using the program STELLS, even while not accounting for uncertainty in the gene trees, tended to have better performance than STEM for a large simulated data set ( loci on 8 taxa) and worse performance on fewer loci [24]. Which method is optimal for inferring species trees or networks might depend on many factors such as the number of loci, the number of lineages sampled per species, the accuracy with which branch lengths can be estimated, the extent to which there are model violations, and the speciation history [49].
Recombination and population size assumptions
Two common assumptions in multispecies coalescent models are that there is no recombination within loci (and free recombination between loci) and that ancestral population sizes are constant.
Recombination can lead to different portions of a gene alignment effectively having distinct gene tree topologies. Ideally, alignments should be chosen so that recombination within genes is unlikely. This can be achieved by testing alignments beforehand for recombination using many available methods [50]–[52], or for whole genome data, choosing the cutoffs for loci such that they are unlikely to occur at recombination breakpoints [53]. In addition, recombination may lead to greater violations of the coalescent model for branch lengths than for topologies [53], so that topologybased methods might be less sensitive to the assumption that there is no recombination within loci. In addition, a recent simulation study found that recombination within loci did not have much impact on species tree inference methods for a wide range of recombination rates [54].
Coalescent models often assume that ancestral populations have constant size for the duration of the population (i.e., a constant size for a given branch of the species tree, but not necessarily the same on different branches). The program *BEAST [46] allows for ancestral population sizes to change linearly with time. Nonconstant population sizes will tend to result in branch lengths that make topologies more (or less) starlike for populations that are increasing (or decreasing) in size [55]. One approach to modelling a changing population size would be to break up a branch into intervals that are relatively constant in size. Suppose, for instance that a branch consists of an interval of generations with population size , and generations with size . The total time of the branch in coalescent units is . Although unequal values of can affect the distribution of coalescence times (for example, if but , then coalescence events might be more likely to occur in the interval with size ), the probabilities of topologies arising in this branch are not affected and can be calculated just using the total time . In particular, for the functions , which are the terms that depend on time in the calculations for gene tree topology probabilities, we havewhich is an instance of the ChapmanKolmogorov equations because the number of lineages is a continuous time Markov chain (a death chain) [56].
We expect that topologybased methods may show more robustness to recombination and changing population sizes than approaches which explicitly model coalescence times. However, for estimating species trees and networks from gene trees, as in other areas of statistical inference, there is likely to be a tradeoff between power and robustness for methods that do and do not model branch lengths of the gene trees.
Searching for networks
A current limitation to the procedure we have outlined for estimating hybridization is that we require a set of candidate networks on which to perform model selection. In some cases, such a set of candidate networks can be obtained by considering specific hypotheses related to biogeographical information. Candidate networks can also be generated using supernetworks from gene trees [57] or other network methods [9]. Often these methods will generate very complicated networks if there are many conflicts in the data, so it might be useful to choose different random subsets of wellsupported (or frequently occurring) gene tree topologies to generate candidate species networks. In the future it will be desirable to develop algorithms that directly search the space of species networks in order to automate searching for optimal species networks.
Supporting Information
Zdroje
1. DoyleJJ 1992 Gene trees and species trees: molecular systematics as onecharacter taxonomy. Syst Bot 17 144 163
2. MaddisonW 1997 Gene trees in species trees. Syst Biol 46 523 536
3. EdwardsSV 2009 Is a new and general theory of molecular systematic biology emerging? Evolution 63 1 19
4. SwoffordDOlsenGWaddellPHillisD 1996 Phylogenetic inference. HillisDMableBMoritzC Molecular Syst Biol.s Sunderland, Mass. Sinauer Assoc 407 514
5. RosenbergNA 2002 The probability of topological concordance of gene trees and species trees. Theor Pop Biol 61 225 247
6. DegnanJHRosenbergNA 2009 Gene tree discordance, phylogenetic inference and the multispecies coalescent. Trends Ecol Evol 24 332 340
7. ArnoldML 1997 Natural Hybridization and Evolution Oxford Oxford University Press
8. MalletJ 2007 Hybrid speciation. Nature 446 279 283
9. HusonDRuppRScornavaccaC 2010 Phylogenetic Networks: Concepts, Algorithms and Applications New York Cambridge University Press
10. NakhlehL 2010 Evolutionary phylogenetic networks: models and issues. HeathLRamakrishnanN The Problem Solving Handbook for Computational Biology and Bioinformatics New York Springer 125 158
11. MalletJ 2005 Hybridization as an invasion of the genome. Trends Ecol Evol 20 229 237
12. LinderCRRiesebergLH 2004 Reconstructing patterns of reticulate evolution in plants. Am J Bot 91 1700 1708
13. DegnanJHDeGiorgioMBryantDRosenbergNA 2009 Properties of consensus methods for inferring species trees from gene trees. Syst Biol 58 35 54
14. ThanCVRosenbergNA 2011 Consistency properties of species tree inference by minimizing deep coalescences. J Comput Biol 18 1 15
15. WangYDegnanJH 2011 Performance of matrix representation with parsimony for inferring species from gene trees. Stat Appl Genet Mol 10 21
16. AnéC 2010 Reconstructing concordance trees and testing the coalescent model from genome wide data sets. KnowlesLLKubatkoLS Estimating species trees: Theoretical and practical aspects Hoboken, NJ WileyBlackwell 35 52
17. AllmanESDegnanJHRhodesJA 2011 Identifying the rooted species tree from the distribution of unrooted gene trees under the coalescent. J Math Biol 62 833 862
18. AllmanESDegnanJHRhodesJA 2011 Determining species tree topologies from clade probabilities under the coalescent. J Theor Biol 289 96 106
19. KnowlesLLCarstensBC 2007 Delimiting species without monophyletic gene trees. Syst Biol 56 887 895
20. KubatkoLSDegnanJH 2007 Inconsistency of phylogenetic estimates from concatenated data under coalescence. Syst Biol 56 17 24
21. LiuLYuLPearlDKEdwardsSV 2009 Estimating species phylogenies using coalescence times among sequences. Syst Biol 58 468 477
22. DeGiorgioMDegnanJH 2010 Fast and consistent estimation of species trees using supermatrix rooted triples. Mol Biol Evol 27 552 569
23. CarstensBKnowlesLL 2007 Estimating species phylogeny from genetree probabilities despite incomplete lineage sorting: an example from Melanoplus grasshoppers. Syst Biol 56 400 411
24. WuY 2012 Coalescentbased species tree inference from gene tree topologies under incomplete lineage sorting by maximum likelihood. Evolution 66 763 775
25. AnéCLargetBBaumDASmithSDRokasA 2007 Bayesian estimation of concordance factors. Mol Biol Evol 24 412 426
26. DegnanJHSalterLA 2005 Gene tree distributions under the coalescent process. Evolution 59 24 37
27. ThanCRuthsDInnanHNakhlehL 2007 Confounding factors in HGT detection: Statistical error, coalescent effects, and multiple solutions. J Comput Biol 14 517 535
28. MengCKubatkoLS 2009 Detecting hybrid speciation in the presence of incomplete lineage sorting using gene tree incongruence: A model. Theor Popul Biol 75 35 45
29. KubatkoLS 2009 Identifying hybridization events in the presence of coalescence via model selection. Syst Biol 58 478 488
30. YuYThanCDegnanJHNakhlehL 2011 Coalescent histories on phylogenetic networks and detection of hybridization despite incomplete lineage sorting. Syst Biol 60 138 149
31. AkaikeH 1974 A new look at the statistical model identification. IEEE Trans Automat Contr 19 716 723
32. BurnhamKAndersonD 2002 Model selection and multimodel inference: a practicaltheoretic approach New York Springer Verlag, 2nd edition
33. SchwarzG 1978 Estimating the dimension of a model. Ann Stat 6 461 464
34. ThanCRuthsDNakhlehL 2008 PhyloNet: a software package for analyzing and reconstructing reticulate evolutionary relationships. BMC Bioinformatics 9 322
35. RokasAWilliamsBLKingNCarrollSB 2003 Genomescale approaches to resolving incongruence in molecular phylogenies. Nature 425 798 804
36. ThanCNakhlehL 2009 Species tree inference by minimizing deep coalescences. PLoS Comput Biol 5 e1000501 doi:10.1371/journal.pcbi.1000501
37. HuelsenbeckJPRonquistF 2001 MRBAYES: Bayesian inference of phylogenetic trees. Bioinformatics 17 754 755
38. SwoffordDL 1996 PAUP*: Phylogenetic analysis using parsimony (and other methods). Sinauer Associates, Underland, Massachusetts, Version 4.0
39. EdwardsSVLiuLPearlDK 2007 Highresolution species trees without concatenation. Proc Natl Acad Sci U S A 104 5936 5941
40. BloomquistEWSuchardMA 2010 Unifying vertical and nonvertical evolution: A stochastic ARGbased framework. Syst Biol 59 27 41
41. PollardDAIyerVNMosesAMEisenMB 2006 Widespread discordance of gene trees with species tree in Drosophila: evidence for incomplete lineage sorting. PLoS Genet 2 e173 doi:10.1371/journal.pgen.0020173
42. NeiM 1987 Molecular Evolutionary Genetics New York Columbia University Press
43. SlatkinM 2008 Linkage disequilibrium — understanding the evolutionary past and mapping the medical future. Nature Rev Genet 9 477 485
44. RannalaBYangZ 2003 Bayes estimation of species divergence times and ancestral population sizes using DNA sequences from multiple loci. Genetics 164 1645 1656
45. LiuLPearlDK 2007 Species trees from gene trees: Reconstructing Bayesian posterior distributions of a species phylogeny using estimated gene tree distributions. Syst Biol 56 504 514
46. HeledJDrummondAJ 2010 Bayesian inference of species trees from multilocus data. Mol Biol Evol 27 570 580
47. LeachéADRannalaB 2011 The accuracy of species tree estimation under simulation: A com parison of methods. Syst Biol 60 126 137
48. KubatkoLSCarstensBCKnowlesLL 2009 STEM: species tree estimation using maximum likelihood for gene trees under coalescence. Bioinformatics 25 971 973
49. HuangHHeQKubatkoLSKnowlesLL 2010 Sources of error inherent in speciestree estimation: Impact of mutational and coalescent effects on accuracy and implications for choosing among different methods. Syst Biol 59 573 583
50. PosadaDCrandallKA 2001 Evaluation of methods for detecting recombination from dna sequences: Computer simulations. P Natl Acad Sci USA 98 13757 13762
51. BruenTCPhilippeHBryantD 2002 A simple and robust statistical test for detecting the presence of recombination. Genetics 172 2665 2681
52. RuthsDNakhlehL 2006 RECOMP: A parsimonybased method for detecting recombination. 59 68 In: Proceedings of the 4th Asia Pacific Bioinformatics Conference
53. AnéC 2011 Detecting phylogenetic breakpoints and discordance from genomewide alignments for species tree reconstruction. Genome Biol Evol 3 246 258
54. LanierHKnowlesL 2012 Is recombination a problem for speciestree analyses? Syst Biol In press: DOI:10.1093/sysbio/syr128
55. WakeleyJ 2008 Coalescent Theory Greenwood Village, CO Roberts & Company
56. RossSM 2010 Introduction to Probability Models New York Academic Press, 10th edition
57. HollandBBenthinSLockhartPMoultonVHuberK 2008 Using supernetworks to distinguish hybridization from lineagesorting. BMC Evol Biol 8 202
Štítky
Genetika Reprodukční medicínaČlánek vyšel v časopise
PLOS Genetics
2012 Číslo 4
Nejčtenější v tomto čísle
Tomuto tématu se dále věnují…
 Insulin Signaling Mediates Sexual Attractiveness in
 Formation of Rigid, NonFlight Forewings (Elytra) of a Beetle Requires Two Major Cuticular Proteins
 ContextDependent Dual Role of SKI8 Homologs in mRNA Synthesis and Turnover
 Runs of Homozygosity Implicate Autozygosity as a Schizophrenia Risk Factor
Zvyšte si kvalifikaci online z pohodlí domova
Léčba karcinomu močového měchýře
nový kurzVšechny kurzy