Substitution Models

Phylogenetic inference of nucleotide data using RevBayes

Sebastian Höhna, Michael Landis, Brian Moore and Tracy Heath

Last modified on December 10, 2018

Overview


This tutorial provides the first protocol from Höhna et al. (2017). Here, we demonstrate how to set up and perform analyses using common nucleotide substitution models. The substitution models used in molecular evolution are continuous time Markov models, which are fully characterized by their instantaneous-rate matrix:

where $\mu_{ij}$ represents the instantaneous rate of substitution from state $i$ to state $j$. The diagonal elements $\mu_i$ are the rates of not changing out of state $i$, equal to the sum of the elements in the corresponding row. Given the instantaneous-rate matrix, $Q$, we can compute the corresponding transition probabilities for a branch of length $t$, $P(t)$, by exponentiating the rate matrix:

Each specific substitution model has a uniquely defined instantaneous-rate matrix, $Q$.

In this tutorial you will perform phylogeny inference under common models of DNA sequence evolution: JC, F81, HKY85, GTR, GTR+Gamma and GTR+Gamma+I. For all of these substitution models, you will perform a Markov chain Monte Carlo (MCMC) analysis to estimate phylogeny and other model parameters. The estimated trees will be unrooted trees with independent branch-length parameters. We will provide comments on how to modify the tutorial if you wish to estimate rooted, clock-like trees. All the assumptions will be covered in more detail later in this tutorial.

Specific functions for substitution models available in RevBayes.
Model Reference Function Parameters
Jukes-Cantor (Jukes and Cantor 1969) fnJC -
K80 (a.k.a. K2P) (Kimura 1980) fnK80 $\kappa$
Felsenstein-81 (Felsenstein 1981) fnF81 $\pi$
T92 (Tamura 1992) fnT92 $\pi_{GC}$, $\kappa$
HKY (Hasegawa et al. 1985) fnHKY $\pi$, $\kappa$
GTR (Tavaré 1986) fnGTR $\pi$, $\epsilon$

Example: Character Evolution under the Jukes-Cantor Substitution Model


Getting Started


The first section of this exercise involves:

  1. setting up a Jukes-Cantor (JC) substitution model for an alignment of the cytochrome b subunit;
  2. approximating the posterior probability of the tree topology and node ages (and all other parameters) using MCMC, and;
  3. summarizing the MCMC output by computing the maximum a posteriori tree.

Graphical model representation of a simple phylogenetic model. The graphical model shows the dependencies between the parameters (Höhna et al. 2014). Here, the rate matrix $Q$ is a constant variable because it is fixed and does not depend on any parameter.The only free parameters of this model, the Jukes-Cantor model, are the tree $\Psi$ including the branch lengths.

We first consider the simplest substitution model described by Jukes and Cantor (1969). The instantaneous-rate matrix for the JC substitution model is defined as

which has the advantage that the transition probability matrix can be computed analytically

where $t$ is the branch length in units of time, and $r$ is the rate (clock) for the process. In the later exercises you will be asked to specify more complex substitution models. Don’t worry, you won’t have to calculate all of the transition probabilities, because RevBayes will take care of all the computations for you. Here we only provide some of the equations for the models in case you might be interested in the details. You will be able to complete the exercises without understanding the underlying math.

The file for this example analysis are provided for you (mcmc_JC.Rev). If you download this file and place it in a directory called scripts inside your main tutorial directory, you can easily execute this analysis using the source() function in the RevBayes console:

source("scripts/mcmc_JC.Rev")

If everything loaded properly, then you should see the program initiate the Markov chain Monte Carlo analysis that estimates the posterior distribution. If you continue to let this run, then you will see it output the states of the Markov chain once the MCMC analysis begins.

Ultimately, this is how you will execute most analyses in RevBayes, with the full specification of the model and analyses contained in the sourced files. You could easily run this entire analysis on your own data by substituting your data file name for that in the model-specification file. However, it is important to understand the components of the model to be able to take full advantage of the flexibility and richness of RevBayes. Furthermore, without inspecting the Rev scripts sourced in mcmc_JC.Rev, you may end up inadvertently performing inappropriate analyses on your dataset, which would be a waste of your time and CPU cycles. The next steps will walk you through the full specification of the model and MCMC analyses.

Loading the Data


First create a directory for this tutorial and name it RB_CTMC_Tutorial, or any name you like.

Navigate to this new directory and create a new folder called data inside of it.

Download the data file called primates_and_galeopterus_cytb.nex and save it to the data directory.

Now start RevBayes from your working directory (RB_CTMC_Tutorial).

Checking and Changing Your Working Directory

For this tutorial and much of the work you will do in RevBayes, you will need to access files. It is important that you are aware of your current working directory if you use relative file paths in your Rev scripts or in the RevBayes console.

To check your current working directory, use the function getwd().

getwd()
/Users/tombayes/Work

If you want to change the directory, enter the path to your directory in the arguments of the function setwd().

setwd("Tutorials/RB_CTMC_Tutorial")

Now check your directory again to make sure you are where you want to be:

getwd()
/Users/tombayes/Work/Tutorials/RB_CTMC_Tutorial

First load in the sequences using the readDiscreteCharacterData() function.

data <- readDiscreteCharacterData("data/primates_and_galeopterus_cytb.nex")

Executing these lines initializes the data matrix as the respective Rev variables. To report the current value of any variable, simply type the variable name and press enter. For the data matrix, this provides information about the alignment:

data
   DNA character matrix with 23 taxa and 1141 characters
   =====================================================
   Origination:                      primates_and_galeopterus_cytb.nex
   Number of taxa:                   23
   Number of included taxa:          23
   Number of characters:             1141
   Number of included characters:    1141
   Datatype:                         DNA

Next we will specify some useful variables based on our dataset. The variable data has member functions that we can use to retrieve information about the dataset. These include, for example, the number of species and the taxa. We will need that taxon information for setting up different parts of our model.

num_taxa <- data.ntaxa()
num_branches <- 2 * num_taxa - 3
taxa <- data.taxa()

Additionally, we set up a (vector) variable that holds all the moves for our analysis. Recall that moves are algorithms used to propose new parameter values during the MCMC simulation. Similarly, we set up a variable for the monitors. Monitors print the values of model parameters to the screen and/or log files during the MCMC analysis.

moves    = VectorMoves()
monitors = VectorMonitors()

You may have noticed that we used the = operator to create the move index. This simply means that the variable is not part of the model. You will later see that we use this operator more often, e.g., when we create moves and monitors.

With the data loaded, we can now proceed to specify our specifying the model.

Setting up the Graphical Model and MCMC


Estimating an unrooted tree under the JC model requires specification of two main components: (1) the and (2) the .

Jukes-Cantor Substitution Model


A given substitution model is defined by its corresponding instantaneous-rate matrix, $Q$. The Jukes-Cantor substitution model does not have any free parameters (as the substitution rates are all assumed to be equal, and there is a separate parameter that scales their overall magnitude), so we can define it as a constant variable. The function fnJC(n) will create an instantaneous-rate matrix for a character with $n$ states. Since we use DNA data here, we create a 4x4 instantaneous-rate matrix:

Q <- fnJC(4) 

You can see the rates of the $Q$ matrix by typing

Q
   [ [ -1.0000, 0.3333, 0.3333, 0.3333 ] ,
     0.3333, -1.0000, 0.3333, 0.3333 ] ,
     0.3333, 0.3333, -1.0000, 0.3333 ] ,
     0.3333, 0.3333, 0.3333, -1.0000 ] ]

As you can see, all substitution rates are equal.

Tree Topology and Branch Lengths


The tree topology and branch lengths are stochastic nodes in our phylogenetic model. In , the tree topology is denoted $\Psi$ and the length of the branch leading to node $i$ is $bl_i$.

We will assume that all possible labeled, unrooted tree topologies have equal probability. This is the dnUniformTopology() distribution in RevBayes. Note that in RevBayes it is advisable to specify the outgroup for your study system if you use an unrooted tree prior, whereas other software, e.g.,
MrBayes uses the first taxon in the data matrix file as the outgroup. Specify the topology stochastic node by passing in the list of taxa to the dnUniformTopology() distribution:

out_group = clade("Galeopterus_variegatus")
topology ~ dnUniformTopology(taxa, outgroup=out_group)

Some types of stochastic nodes can be updated by a number of alternative moves. Different moves may explore parameter space in different ways, and it is possible to use multiple different moves for a given parameter to improve mixing (the efficiency of the MCMC simulation). In the case of our unrooted tree topology, for example, we can use both a nearest-neighbor interchange move (mvNNI) and a subtree-prune and regrafting move (mvSPR). These moves do not have tuning parameters associated with them, thus you only need to pass in the topology node and proposal weight.

moves.append( mvNNI(topology, weight=num_taxa) )
moves.append( mvSPR(topology, weight=num_taxa/10.0) )

The weight specifies how often the move will be applied either on average per iteration or relative to all other moves. Have a look at the MCMC Diagnosis tutorial for more details about moves and MCMC strategies (found in Tutorials).

Next we have to create a stochastic node for each of the $2N - 3$ branches in our tree (where $N=$ n_species). We can do this using a for loop — this is a plate in our graphical model. In this loop, we can create each of the branch-length nodes and assign each move. Copy this entire block of Rev code into the console:

for (i in 1:num_branches) {
   br_lens[i] ~ dnExponential(10.0)
   moves.append( mvScale(br_lens[i]) )
}

It is convenient for monitoring purposes to add the tree length as deterministic variable. The tree length is simply the sum of all branch lengths. Accordingly, the tree length can be computed using the sum() function, which calculates the sum of any vector of values.

TL := sum(br_lens)

Finally, we can create a phylogram (a phylogeny in which the branch lengths are proportional to the expected number of substitutions/site) by combining the tree topology and branch lengths. We do this using the treeAssembly() function, which applies the value of the $i^{th}$ member of the br_lens vector to the branch leading to the $i^{th}$ node in topology. Thus, the psi variable is a deterministic node:

psi := treeAssembly(topology, br_lens)

Alternative tree priors

For large phylogenetic trees, i.e., with more than 200 taxa, it might be easier to specify a combined topology and branch length prior distribution. We can achieve this by simple using the distribution dnUniformTopologyBranchLength().

br_len_lambda <- 10.0
psi ~ dnUniformTopologyBranchLength(taxa, branchLengthDistribution=dnExponential(br_len_lambda))
moves.append( mvNNI(psi, weight=num_taxa) )
moves.append( mvSPR(psi, weight=num_taxa/10.0) )
moves.append( mvBranchLengthScale(psi, weight=num_branches) )

You might think that this approach is in fact simpler than the for loop that we explained above. We still think that it is pedagogical to specify the prior on each branch length separately in this tutorial to emphasize all components of the model.

Alternative branch-length priors

Some studies, e.g. (Brown et al. 2010) (Rannala et al. 2012), have criticized the exponential prior distribution for branch lengths because it induces a gamma-distributed tree-length and the mean of this gamma distribution grows with the number of taxa. For example, we can use instead a specific gamma prior distribution (or any other distribution defined on a positive real variable) for the tree length, and then use a Dirichlet prior distribution to break the tree length into the corresponding branch lengths (Zhang et al. 2012).

First, specify a prior distribution on the tree length with your desired mean. For example, we use a gamma distribution as our prior on the tree length.

TL ~ dnGamma(2,4)
moves.append( mvScale(TL) )

Now we create a random variable for the relative branch lengths.

rel_branch_lengths ~ dnDirichlet( rep(1.0,num_branches) )
moves.append( mvBetaSimplex(rel_branch_lengths, weight=num_branches) )
moves.append( mvDirichletSimplex(rel_branch_lengths, weight=num_branches/10.0) )

Finally, transform the relative branch lengths into actual branch lengths

br_lens := rel_branch_lengths * TL

Alternative Prior on Time-Trees: Tree Topology and Node Ages

Alternatively, you may want to specify a prior on time-trees. Here we will briefly indicate how to specify such an prior which will lead to inference of time trees.

The tree (the topology and node ages) is a stochastic node in our phylogenetic model. For simplicity, we will assume a uniform prior on both topologies and node ages. The distribution in RevBayes is dnUniformTimeTree().

Fore more information on tree priors, such as birth-death processes, please read the Relaxed Clocks & Time Trees.

First, we need to specify the age of the tree:

root_age <- 10.0

Here we simply assumed that the tree is 10.0 time units old. We could also specify a prior on the root age if we have fossil calibrations (see Relaxed Clocks & Time Trees). Next, we specify the tree stochastic variable by passing in the taxon information taxa to the dnUniformTimeTree() distribution:

psi ~ dnUniformTimeTree(rootAge=root_age, taxa=taxa)

Some types of stochastic nodes can be updated by a number of alternative moves. Different moves may explore parameter space in different ways,and it is possible to use multiple different moves for a given parameter to improve mixing (the efficiency of the MCMC simulation). In the case of our rooted tree, for example, we can use both a nearest-neighbor interchange move without and with changing the node ages (mvNarrow and mvNNI) and a fixed-node-height subtree-prune and regrafting move (mvFNPR) and its Metropolized-Gibbs variant (mvGPR) (Höhna et al. 2008; Höhna and Drummond 2012). We also need moves that change the ages of the internal nodes, for example, mvSubtreeScale and mvNodeTimeSlideUniform. These moves do not have tuning parameters associated with them, thus you only need to pass in the psi node and proposal weight.

moves.append( mvNarrow(psi, weight=num_taxa) )
moves.append( mvNNI(psi, weight=num_taxa/5.0) )
moves.append( mvFNPR(psi, weight=num_taxa/5.0) )
moves.append( mvGPR(psi, weight=num_taxa/30.0) )
moves.append( mvSubtreeScale(psi, weight=num_taxa/3.0) )
moves.append( mvNodeTimeSlideUniform(psi, weight=num_taxa) )

The weight specifies how often the move will be applied either on average per iteration or relative to all other moves. Have a look at the Diagnosing MCMC performance for more details about moves and MCMC strategies.

Molecular Clock


Additionally, in the case of time-calibrated trees, we need to add a molecular clock rate parameter. For example, we know from empirical estimates that the molecular clock rate is about 0.01 (=1%) per million years per site. Nevertheless, we can estimate it here because we fixed the root age. We use a uniform prior on the log-transform clock rate. This specifies our lack of prior knowledge on the magnitude of the clock rate.

log_clock_rate ~ dnUniform(-6,1)
moves.append( mvSlide(log_clock_rate, weight=2.0) )
clock_rate := 10^log_clock_rate

Instead, you could also fix the clock rate and estimate the root age. For more information on molecular clocks please read the Relaxed Clocks & Time Trees tutorial.

Putting it All Together


We have fully specified all of the parameters of our phylogenetic model—the tree topology with branch lengths, and the substitution model that describes how the sequence data evolved over the tree with branch lengths. Collectively, these parameters comprise a distribution called the phylogenetic continuous-time Markov chain, and we use the dnPhyloCTMC constructor function to create this node. This distribution requires several input arguments:

  1. the tree with branch lengths;
  2. the instantaneous-rate matrix Q;
  3. the type of character data.

Build the random variable for the character data (sequence alignment).

seq ~ dnPhyloCTMC(tree=psi, Q=Q, type="DNA")

Once the PhyloCTMC model has been created, we can attach our sequence data to the tip nodes in the tree.

seq.clamp(data)

[Note that although we assume that our sequence data are random variables—they are realizations of our phylogenetic model—for the purposes of inference, we assume that the sequence data are “clamped”.] When this function is called, RevBayes sets each of the stochastic nodes representing the tips of the tree to the corresponding nucleotide sequence in the alignment. This essentially tells the program that we have observed data for the sequences at the tips.

Finally, we wrap the entire model to provide convenient access to the DAG. To do this, we only need to give the model() function a single node. With this node, the model() function can find all of the other nodes by following the arrows in the graphical model:

mymodel = model(Q)

Now we have specified a simple phylogenetic analysis—each parameter of the model will be estimated from every site in our alignment. If we inspect the contents of mymodel we can review all of the nodes in the DAG:

mymodel

Specifying Monitors and Output Files


For our MCMC analysis, we need to set up a vector of monitors to record the states of our Markov chain. The monitor functions are all called mn\*, where \* is the wild-card representing the monitor type. First, we will initialize the model monitor using the mnModel function. This creates a new monitor variable that will output the states for all model parameters when passed into a MCMC function.

monitors.append( mnModel(filename="output/primates_cytb_JC.log", printgen=10) )

The mnFile monitor will record the states for only the parameters passed in as arguments. We use this monitor to specify the output for our sampled trees and branch lengths.

monitors.append( mnFile(filename="output/primates_cytb_JC.trees", printgen=10, psi) )

Finally, create a screen monitor that will report the states of specified variables to the screen with mnScreen:

monitors.append( mnScreen(printgen=1000, TL) )

This monitor mostly helps us to see the progress of the MCMC run.

Initializing and Running the MCMC Simulation


With a fully specified model, a set of monitors, and a set of moves, we can now set up the MCMC algorithm that will sample parameter values in proportion to their posterior probability. The mcmc() function will create our MCMC object:

mymcmc = mcmc(mymodel, monitors, moves, nruns=2, combine="mixed")

Notice that we also specified nruns=2 which means that RevBayes will automatically run 2 independent MCMC runs. You will find that the output is created in two files with extension _run_1 and _run_2 for each replicate and additionally the samples from both runs are combined into one file for more convenient post-processing. Now, run the MCMC:

mymcmc.run(generations=20000,tuningInterval=200)

When the analysis is complete, you will have the monitored files in your output directory.

Summarizing MCMC Samples


Methods for visualizing the marginal densities of parameter values are not currently available in RevBayes itself. Thus, it is important to use programs like Tracer (Rambaut and Drummond 2011) to evaluate mixing and non-convergence.

Look at the file called output/primates_cytb_JC.log in Tracer. There you see the posterior distribution of the continuous parameters, e.g., the tree length variable TL.

Left: Trace of tree-length samples for one MCMC run. The caterpillar-like look is a good sign.You will also see that the effective sample size is comparably large, i.e., much larger than 200. Right: Posterior distribution of the tree length of the primate phylogeny under a Jukes-Cantor substitution model.

It is always important to carefully assess the MCMC samples for the various parameters in your analysis. You can read more about MCMC tuning and evaluating and improving mixing in the tutorials Introduction to MCMC using RevBayes and Diagnosing MCMC Performance.

Exercise 1


We are interested in the phylogenetic relationship of the Tarsiers. Therefore, we need to summarize the trees sampled from the posterior distribution. RevBayes can summarize the sampled trees by reading in the tree-trace file:

treetrace = readTreeTrace("output/primates_cytb_JC.trees", treetype="non-clock", outgroup=out_group)

The mapTree() function will summarize the tree samples and write the maximum a posteriori tree to file:

map_tree = mapTree(treetrace,"output/primates_cytb_JC_MAP.tree")

Maximum a posteriori estimate of the primate phylogeny under a Jukes-Cantor substitution model. The numbers at the nodes show the posterior probabilities for the clades.We have rooted the tree at the outgroup Galeopterus_variegatus

Look at the file called output/primates_cytb_JC_MAP.tree in FigTree. We show it in .

Fill in the following table as you go through the tutorial.

Posterior probabilities under different analyses
Model Lemuroidea Lorisoidea Platyrrhini Catarrhini
Jukes-Cantor        
HKY85        
F81        
GTR        
GTR+Gamma        
GTR+Gamma+I        

Note, you can query the posterior probability of a clade being monophyletic using the following command:

Lemuroidea <- clade("Cheirogaleus_major", 
                    "Daubentonia_madagascariensis", 
                    "Lemur_catta", 
                    "Lepilemur_hubbardorum",
                    "Microcebus_murinus",
                    "Propithecus_coquereli",
                    "Varecia_variegata_variegata")
                    
treetrace.cladeProbability( Lemuroidea )
Primate and species relationships.
Species Family Parvorder Suborder
Aotus trivirgatus Aotidae Platyrrhini (NWM) Haplorrhini
Callicebus donacophilus Pitheciidae Platyrrhini (NWM) Haplorrhini
Cebus albifrons Cebidae Platyrrhini (NWM) Haplorrhini
Cheirogaleus major Cheirogaleidae Lemuroidea Strepsirrhini
Chlorocebus aethiops Cercopithecoidea Catarrhini Haplorrhini
Colobus guereza Cercopithecoidea Catarrhini Haplorrhini
Daubentonia madagascariensis Daubentoniidae Lemuroidea Strepsirrhini
Galago senegalensis Galagidae Lorisidae Strepsirrhini
Hylobates lar Hylobatidea Catarrhini Haplorrhini
Lemur catta Lemuridae Lemuroidea Strepsirrhini
Lepilemur hubbardorum Lepilemuridae Lemuroidea Strepsirrhini
Loris tardigradus Lorisidae Lorisidae Strepsirrhini
Macaca mulatta Cercopithecoidea Catarrhini Haplorrhini
Microcebus murinus Cheirogaleidae Lemuroidea Strepsirrhini
Nycticebus coucang Lorisidae Lorisidae Strepsirrhini
Otolemur crassicaudatus Galagidae Lorisidae Strepsirrhini
Pan paniscus Hominoidea Catarrhini Haplorrhini
Perodicticus potto Lorisidae Lorisidae Strepsirrhini
Propithecus coquereli Indriidae Lemuroidea Strepsirrhini
Saimiri sciureus Cebidae Platyrrhini (NWM) Haplorrhini
Tarsius syrichta Tarsiidae Tarsiiformes Haplorrhini
Varecia variegata variegata Lemuridae Lemuroidea Strepsirrhini

Setting up the Kimura 1980 (K80 or K2P) substitution model

The K80 model (AKA the K2P model) allows the rates of transition and transversion substitutions to be unequal (Kimura 1980). The parameter $\kappa$ describes the relative rate of transition to transversion substitutions (if $\kappa > 1$, transitions occur at a higher rate than transversions). The instantaneous-rate matrix for the K80 model is defined as:

Now, add the parameter $\kappa$ to the substitution model, and create a K80 rate matrix:

kappa ~ dnExp(1)
moves.append( mvScale(kappa, weight=1.0) )

Q := fnK80(kappa)

The Hasegawa-Kishino-Yano (HKY) 1985 Substitution Model


The Jukes-Cantor model assumes that all substitution rates are equal, which also implies that the stationary frequencies of the four nucleotide bases are equal. These assumptions are not very biologically reasonable, so we might wish to consider a more realistic substitution model that relaxes some of these assumptions. For example, we might allow stationary frequencies, $\pi$, to be unequal, and allow rates of transition and transversion substitutions to differ, $\kappa$. This corresponds to the substitution model proposed by (Hasegawa et al. 1985), which is specified with the following instantaneous-rate matrix:

where the diagonal ${\cdot}$ entries are equal to the negative sum of the elements in the corresponding row.

Use the file mcmc_JC.Rev as a starting point for the HKY analysis.

Note that we are adding two new variables to our model. We can define a variable pi for the stationary frequencies that are drawn from a flat Dirichlet distribution by

pi_prior <- v(1,1,1,1) 
pi ~ dnDirichlet(pi_prior)

Since pi is a stochastic variable, we need to specify a move to propose updates to it. A good move on variables drawn from a Dirichlet distribution is the mvBetaSimplex. This move randomly takes an element from the simplex, proposes a new value for it drawn from a Beta distribution, and then rescales all values of the simplex to sum to 1 again.

moves.append( mvBetaSimplex(pi, weight=2) )
moves.append( mvDirichletSimplex(pi, weight=1) )

The second new variable is $\kappa$, which specifies the ratio of transition-transversion rates. The $\kappa$ parameter must be a positive-real number and a natural choice as the prior distribution is the lognormal distribution:

kappa ~ dnLognormal(0.0, 1.0)

Again, we need to specify a move for this new stochastic variable. A simple scaling move should do the job.

moves.append( mvScale(kappa) )

Finally, we need to create the HKY instantaneous-rate matrix using the fnHKY function:

Q := fnHKY(kappa,pi)

This should be all for the HKY model. Don’t forget to change the output file names, otherwise your old analyses files will be overwritten.

Exercise 2


The General Time-Reversible (GTR) Substitution Model


The HKY substitution model can accommodate unequal base frequencies and different rates of transition and transversion substitutions. Despite these extensions, the HKY model may still be too simplistic for many real datasets. Here, we extend the HKY model to specify the General Time Reversible (GTR) substitution model (Tavaré 1986), which allows all six exchangeability rates to differ ().

The instantaneous-rate matrix for the GTR substitution model is:

where the six exchangeability parameters, $r_{ij}$, specify the relative rates of change between states $i$ and $j$.

Graphical model representation of the general-time reversible (GTR) phylogenetic model.

The GTR model requires that we define and specify a prior on the six exchangeability rates, which we will describe using a flat Dirichlet distribution. As we did previously for the Dirichlet prior on base frequencies, we first define a constant node specifying the vector of concentration-parameter values using the v() function:

er_prior <- v(1,1,1,1,1,1) 

This node defines the concentration-parameter values of the Dirichlet prior distribution on the exchangeability rates. Now, we can create a stochastic node for the exchangeability rates using the dnDirichlet() function, which takes the vector of concentration-parameter values as an argument and the ~ operator. Together, these create a stochastic node named er ($\theta$ in ):

er ~ dnDirichlet(er_prior)

The Dirichlet distribution assigns probability densities to a group of parameters: e.g., those that measure proportions and must sum to 1. Here, we have specified a six-parameter Dirichlet prior, where each value describes one of the six relative rates of the GTR model: (1) $A\leftrightarrows C$; (2) $A\leftrightarrows G$; (3) $A\leftrightarrows T$; (4) $C\leftrightarrows G$; (5) $C\leftrightarrows T$; (6) $G\leftrightarrows T$. The input parameters of a Dirichlet distribution are called shape (or concentration) parameters. The expectation and variance for each variable are related to the sum of the shape parameters. The prior we specified above is a ‘flat’ or symmetric Dirichlet distribution; all of the shape parameters are equal (1,1,1,1,1,1). This describes a model that allows for equal rates of change between nucleotides, such that the expected rate for each is equal to $\frac{1}{6}$ (a).

We might also parameterize the Dirichlet distribution such that all of the shape parameters were equal to 100, which would also specify a prior with an expectation of equal exchangeability rates (b). However, by increasing the values of the shape parameters, er_prior <- v(100,100,100,100,100,100), the Dirichlet distribution will more strongly favor equal exchangeability rates; (i.e., a relatively informative prior).

Alternatively, we might consider an asymmetric Dirichlet parameterization that could reflect a strong prior belief that transition and transversion substitutions occur at different rates. For example, we might specify the prior density er_prior <- v(4,8,4,4,8,4). Under this model, the expected rate for transversions would be $\frac{4}{32}$ and that for transitions would be $\frac{8}{32}$, and there would be greater prior probability on sets of GTR rates that matched this configuration (c).

Yet another asymmetric prior could specify that each of the six GTR rates had a different value conforming to a Dirichlet(2,4,6,8,10,12). This would lead to a different prior probability density for each rate parameter (d). Without strong prior knowledge about the pattern of relative rates, however, we can better reflect our uncertainty by using a vague prior on the GTR rates. Notably, all patterns of relative rates have the same probability density under er_prior <- v(1,1,1,1,1,1).

Four different examples of Dirichlet priors on exchangeability rates.

For each stochastic node in our model, we must also specify a proposal mechanism if we wish to estimate that parameter. The Dirichlet prior on our parameter er creates a simplex of values that sum to 1.

moves.append( mvBetaSimplex(er, weight=3) )
moves.append( mvDirichletSimplex(er, weight=1) )

We can use the same type of distribution as a prior on the 4 stationary frequencies ($\pi_A, \pi_C, \pi_G, \pi_T$) since these parameters also represent proportions. Specify a flat Dirichlet prior density on the base frequencies:

pi_prior <- v(1,1,1,1) 
pi ~ dnDirichlet(pi_prior)

The node pi represents the $\pi$ node in . Now add the simplex scale move on the stationary frequencies to the moves vector:

moves.append( mvBetaSimplex(pi, weight=2) )
moves.append( mvDirichletSimplex(pi, weight=1) )

We can finish setting up this part of the model by creating a deterministic node for the GTR instantaneous-rate matrix Q. The fnGTR() function takes a set of exchangeability rates and a set of base frequencies to compute the instantaneous-rate matrix used when calculating the likelihood of our model.

Q := fnGTR(er,pi)

Exercise 3


The Discrete Gamma Model of Among Site Rate Variation


Members of the GTR family of substitution models assume that rates are homogeneous across sites, an assumption that is often violated by real data. We can accommodate variation in substitution rate among sites (ASRV) by adopting the discrete-gamma model (Yang 1994). This model assumes that the substitution rate at each site is a random variable that is described by a discretized gamma distribution, which has two parameters: the shape parameter, $\alpha$, and the rate parameter, $\beta$. In order that we can interpret the branch lengths as the expected number of substitutions per site, this model assumes that the mean site rate is equal to 1. The mean of the gamma is equal to $\alpha/\beta$, so a mean-one gamma is specified by setting the two parameters to be equal, $\alpha=\beta$. This means that we can fully describe the gamma distribution with the single shape parameter, $\alpha$. The degree of among-site substitution rate variation is inversely proportional to the value of the $\alpha$-shape parameter. As the value of the $\alpha$-shape increases, the gamma distribution increasingly resembles a normal distribution with decreasing variance, which therefore corresponds to decreasing levels of ASRV (). By contrast, when the value of the $\alpha$-shape parameter is $< 1$, the gamma distribution assumes a concave distribution that concentrates most of the prior density on low rates, but retains some prior mass on sites with very high rates, which therefore corresponds to high levels of ASRV (). Note that, when $\alpha = 1$, the gamma distribution collapses to an exponential distribution with a rate parameter equal to $\beta$.

The probability density of mean-one gamma-distributed rates for different values of the $\alpha$-shape parameter.

We typically lack prior knowledge regarding the degree of ASRV for a given alignment. Accordingly, rather than specifying a precise value of $\alpha$, we can instead estimate the value of the $\alpha$-shape parameter from the data. This requires that we specify a diffuse (relatively ‘uninformative’) prior on the $\alpha$-shape parameter. For this analysis, we will use a lognormal distribution with a mean parameter, alpha_prior_mean, equal to 5.0, and standard deviation, alpha_prior_sd, equal to 0.587405 (thus, 95% of the prior density spans exactly one order of magnitude).

This approach for accommodating ASRV is another example of a hierarchical model (). That is, variation in substitution rates across sites is addressed by applying a site-specific rate multiplier to each of the $j$ sites, $r_j$. These rate-multipliers are drawn from a discrete, mean-one gamma distribution; the shape of this prior distribution (and the corresponding degree of ASRV) is governed by the $\alpha$-shape parameter. The $\alpha$-shape parameter, in turn, is treated as a lognormal distributed random variable. Finally, the shape of the lognormal prior is governed by the mean and standard deviation parameters, which are set to fixed values.

Graphical model representation of the General Time Reversible (GTR) + Gamma phylogenetic model with invariable sites.

Setting up the Gamma Model in RevBayes


Then create a stochastic node called alpha with a uniform prior distribution between 0.0 and $10^8$ (this represents the stochastic node for the $\alpha$-shape parameter in ):

alpha ~ dnUniform( 0.0, 1E8 )
alpha.setValue(1.0)

Note that we initialized the value of alpha to $1.0$. This is strictly speaking not necessary but helps tremendously the MCMC to converge. As a general rule, it is possible to initialize starting values for the MCMC using the setValue( xx ) function, which is available for every stochastic variable, but it might also make your replicated MCMC runs to be more likely to get stuck in the same local area of parameters.

The way the ASRV model is implemented involves discretizing the mean-one gamma distribution into a set number of rate categories, $k$. Thus, we can analytically marginalize over the uncertainty in the rate at each site. The likelihood of each site is averaged over the $k$ rate categories, where the rate multiplier is the mean (or median) of each of the discrete $k$ categories. To specify this, we need a deterministic node that is a vector that will hold the set of $k$ rates drawn from the gamma distribution with $k$ rate categories. The fnDiscretizeGamma() function returns this deterministic node and takes three arguments: the shape and rate of the gamma distribution and the number of categories. Since we want to discretize a mean-one gamma distribution, we can pass in alpha for both the shape and rate.

Initialize the gamma_rates deterministic node vector using the fnDiscretizeGamma() function with 4 bins:

gamma_rates := fnDiscretizeGamma( alpha, alpha, 4 )

Note that here, by convention, we set $k = 4$. The random variable that controls the rate variation is the stochastic node alpha. We will apply a simple scale move to this parameter.

moves.append( mvScale(alpha, weight=2.0) )

Remember that you need to call the PhyloCTMC constructor to include the new site-rate parameter:

seq ~ dnPhyloCTMC(tree=psi, Q=Q, siteRates=gamma_rates, type="DNA")

Exercise 4


Modeling Invariable Sites


All of the substitution models described so far assume that the sequence data are potentially variable. That is, we assume that the sequence data are random variables; specifically, we assume that they are realizations of the specified PhyloCTMC distribution. However, some sites may not be free to vary—when the substitution rate of a site is zero, it is said to be invariable. Invariable sites are often confused with invariant sites—when each species exhibits the same state, it is said to be invariant. The concepts are related but distinct. If a site is truly invariable, it will necessarily give rise to an invariant site pattern, as such sites will always have a zero substitution rate. However, an invariant site pattern may be achieved via multiple substitutions that happen to end in the same state for every species.

Here we describe an extension to our phylogenetic model to accommodate invariable sites. Under the invariable-sites model (Hasegawa et al. 1985), each site is invariable with probability pinvar, and variable with probability $1-$pinvar.

First, let’s have a look at the data and see how many invariant sites we have:

data.getNumInvariantSites()

There seem to be a substantial number of invariant sites.

Now let’s specify the invariable-sites model in RevBayes. We need to specify the prior probability that a site is invariable. A Beta distribution is a common choice for parameters representing probabilities.

pinvar ~ dnBeta(1,1)

The Beta(1,1) distribution is a flat prior distribution that specifies equal probability for all values between 0 and 1.

Then, as usual, we add a move to change this stochastic variable; we’ll use a simple sliding window move.

moves.append( mvSlide(pinvar) )

Finally, you need to call the PhyloCTMC constructor to include the new pinvar parameter:

seq ~ dnPhyloCTMC(tree=psi, Q=Q, siteRates=gamma_rates, pInv=pinvar, type="DNA")

Exercise 5


  1. Brown J.M., Hedtke S.M., Lemmon A.R., Lemmon E.M. 2010. When Trees Grow Too Long: Investigating the Causes of Highly Inaccurate Bayesian Branch-Length Estimates. Systematic Biology. 59:145–161. 10.1093/sysbio/syp081
  2. Felsenstein J. 1981. Evolutionary Trees from DNA Sequences: a Maximum Likelihood Approach. Journal of Molecular Evolution. 17:368–376. 10.1007/BF01734359
  3. Hasegawa M., Kishino H., Yano T. 1985. Dating of the Human-Ape Splitting by a molecular Clock of Mitochondrial DNA. Journal of Molecular Evolution. 22:160–174. 10.1007/BF02101694
  4. Höhna S., Defoin-Platel M., Drummond A.J. 2008. Clock-Constrained Tree Proposal Operators in Bayesian Phylogenetic Inference. 8th IEEE International Conference on BioInformatics and BioEngineering, 2008. BIBE 2008.:1–7.
  5. Höhna S., Drummond A.J. 2012. Guided Tree Topology Proposals for Bayesian Phylogenetic Inference. Systematic Biology. 61:1–11.
  6. Höhna S., Heath T.A., Boussau B., Landis M.J., Ronquist F., Huelsenbeck J.P. 2014. Probabilistic Graphical Model Representation in Phylogenetics. Systematic Biology. 63:753–771. 10.1093/sysbio/syu039
  7. Höhna S., Landis M.J., Heath T.A. 2017. Phylogenetic Inference using RevBayes. Current Protocols in Bioinformatics. 10.1002/cpbi.22
  8. Jukes T.H., Cantor C.R. 1969. Evolution of Protein Molecules. Mammalian Protein Metabolism. 3:21–132. 10.1016/B978-1-4832-3211-9.50009-7
  9. Kimura M. 1980. A simple method for estimating evolutionary rates of base substitutions through comparative studies of nucleotide sequences. Journal of Molecular Evolution. 16:111–120.
  10. Rambaut A., Drummond A.J. 2011. Tracer v1.5. . http://tree.bio.ed.ac.uk/software/tracer/
  11. Rannala B., Zhu T., Yang Z. 2012. Tail Paradox, Partial Identifiability, and Influential Priors in Bayesian Branch Length Inference. Molecular Biology and Evolution. 29:325–335.
  12. Tamura K. 1992. Estimation of the number of nucleotide substitutions when there are strong transition-transversion and G+ C-content biases. Molecular Biology and Evolution. 9:678–687.
  13. Tavaré S. 1986. Some Probabilistic and Statistical Problems in the Analysis of DNA Sequences. Some Mathematical Questions in Biology: DNA Sequence Analysis. 17:57–86.
  14. Yang Z. 1994. Maximum Likelihood Phylogenetic Estimation from DNA Sequences with Variable Rates Over Sites: Approximate Methods. Journal of Molecular Evolution. 39:306–314. 10.1007/BF00160154
  15. Zhang C., Rannala B., Yang Z. 2012. Robustness of Compound Dirichlet Priors for Bayesian Inference of Branch Lengths. Systematic Biology. 61:779–784.