 Research article
 Open Access
In silico segmentations of lentivirus envelope sequences
 Aurélia BoissinQuillon^{1},
 Didier Piau^{2} and
 Caroline Leroux^{1}Email author
https://doi.org/10.1186/14712105899
© BoissinQuillon et al; licensee BioMed Central Ltd. 2007
 Received: 11 August 2006
 Accepted: 21 March 2007
 Published: 21 March 2007
Abstract
Background
The gene encoding the envelope of lentiviruses exhibits a considerable plasticity, particularly the region which encodes the surface (SU) glycoprotein. Interestingly, mutations do not appear uniformly along the sequence of SU, but they are clustered in restricted areas, called variable (V) regions, which are interspersed with relatively more stable regions, called constant (C) regions. We look for specific signatures of C/V regions, using hidden Markov models constructed with SU sequences of the equine, human, small ruminant and simian lentiviruses.
Results
Our models yield clear and accurate delimitations of the C/V regions, when the test set and the training set were made up of sequences of the same lentivirus, but also when they were made up of sequences of different lentiviruses. Interestingly, the models predicted the different regions of lentiviruses such as the bovine and feline lentiviruses, not used in the training set. Models based on composite training sets produce accurate segmentations of sequences of all these lentiviruses.
Conclusion
Our results suggest that each C/V region has a specific statistical oligonucleotide composition, and that the C (respectively V) regions of one of these lentiviruses are statistically more similar to the C (respectively V) regions of the other lentiviruses, than to the V (respectively C) regions of the same lentivirus.
Keywords
 Markov Chain
 Relative Entropy
 Versus Region
 Hide State
 Feline Immunodeficiency Virus
Background
Retroviruses are RNA viruses infecting vertebrates and many non vertebrates. Virus particles are spherical and surrounded by an envelope. Their viral replication is dependent of the RT (Reverse Transcriptase), a viral RNAdependent DNApolymerase. The lentivirus genus is part of the retrovirus family. Lentiviruses infect animals and humans and cause slowly progressing diseases. Among the lentivirus genus, HIV1 and HIV2 (Human Immunodeficiency Virus type 1 and 2) infect humans, EIAV (Equine Infectious Anemia Virus) infects equids, SRLV (Small Ruminant LentiVirus) infects goats and sheep, SIV (Simian Immunodeficiency Virus) infects non primate monkeys, BIV (Bovine Immunodeficiency Virus) infects bovines and FIV (Feline Immunodeficiency Virus) infects felines.
The considerable plasticity of the genome of lentiviruses is quite obvious in the env gene, encoding the envelope, particularly in the region encoding the surface (SU) glycoprotein forming spikes. Causes of this plasticity are, among other factors, the low fidelity of the viral reverse transcriptase (RT) during the retrotranscription of the viral RNA genome into DNA, the lack of proofreading activity of the RT, the high level of virus replication, and some recombination events in coinfected cells [1–4].
Interestingly, SU mutations do not appear uniformly along the env gene, but are clustered in restricted and specific areas defined as variable (V) regions flanked by constant (C) regions. On average, and depending on the lentivirus considered, from 10 % to 35 % of the aminoacids in SU vary between isolates, and more than 70 % of these variable aminoacids are located in V regions. Such C/V segmentations hold for all the lentiviruses [5–11].
It is unclear whether the accumulation of mutations in V regions is mainly due to locally high intrinsic mutation rates, or if mutations occur at similar rates at every SU sites with subsequent selection mechanisms eliminating most variants from the C regions. In any case, the plasticity of these genomes allows them to escape immune control very efficiently, while keeping their identity. Most of amino acids encoded by the V regions are on the outside of SU, while the amino acids encoded by the C regions are in the internal part. In this respect, one should note that the replication acts on onedimensional molecules, at a moment when most of the information about their threedimensional conformation seems unavailable. In other words, if the intrinsic mutation rates are indeed different in C regions and in V regions, this might be due to some specific signals encoded by the nucleotide (linear) viral sequence itself, possibly corresponding to interactions with the RT. To test this hypothesis, we developed a mathematical model based on lentivirus sequences, as simple and robust as possible, able to localize and to characterize their C/V segmentation of the SU region. Our approach was based on HMMs (hidden Markov models). These models are tailored to describe heterogeneous sequences, since they basically break down a given sequence into a succession of locally homogeneous subsequences. HMMs were initially introduced in the context of speech recognition [12] and they are now major tools of the analysis of genomic and proteomic sequences [13–19]. In sequence analysis, each of the subsequences called a region, is described by the value of a Markov chain, called the hidden state, taken from a finite collection of values. Each state is characterized by its own statistical composition in nucleotides or in aminoacids. The succession of states itself is ruled by a master Markov chain, called the hidden chain.
Our main findings are as follows. Using SU sequences of EIAV, HIV, SRLV or SIV to train the HMMs, we obtained clear and accurate delimitations of the C and V regions of these lentiviruses. This suggests that the statistical composition of the C regions is markedly different from the statistical composition of the V regions. Additionally, we developed combined models, based on EIAV, HIV, SIV and SRLV sequences. These were able to predict simultaneously the C and V regions of every lentivirus in the collection above. Our combined models also predicted the C/V segmentation of other lentiviruses which were not used in the training sets: BIV and FIV. This indicates that the C and V regions are statistically distinct and that the V regions of all the lentiviruses share common statistical signatures.
Results
C/V segmentations of EIAV
We first tried to differentiate the C and V regions of the EIAV SU, using HMMs with N = 2 hidden states, for different orders m. The parameters of the models were estimated on training sets of 94 nucleotide sequences, by the EM algorithm. We used various training sets, dividing at random our complete set of sequences into two equal parts (1:1), the training and the test sets. Then, none of the various HMMs was able to identify the C and V regions of the EIAV SU. We obtained hidden states sequences which oscillated and repeatedly jumped from one hidden state to the other (data not shown). Hence, this method was not reliable to identify homogeneous regions corresponding to the C and V regions of the EIAV SU.
By contrast, fixed EM, as described in section Methods, yielded a clear delimitation of the known C and V regions on the whole test set, for HMMs of different order. For example, HMM of order m = 2 allowed us to predict most of the V regions on nucleotide sequences. HMMs of higher orders (m ≥ 3) gave even more accurate prediction. To evaluate the fit quality and to select the best model among the candidates, we used the Akaike information criterion (AIC) [20]. This criterion is defined by
AIC = 2log(L) + 2n,
Modeling of the C and V regions of the EIAV SU.
Number of hidden states  

N = 2  N = 9  
Order  AIC  Order  AIC 
m = 2  250184  m = 2  240054 
m = 3  233586  m = 3  215632 
m = 4  189932  m = 4  180734 
m = 5  138084  m = 5  169786 
m = 6  130774  m = 6  300404 
m = 7  262786 
To differentiate the variable regions V1 to V8 and the C regions, we then used HMMs with N = 9 states on nucleotide sequences. Thus, we trained one hidden state with each variable region and one hidden state with the constant regions as a whole, and we estimated the parameters of a HMM of different orders by the fixed EM algorithm. The best model is of order m = 5 (Table 1). This yields a precise delimitation of the C and V regions on nucleotide sequences, each V region showing a distinct signal (Figure 1B). Estimating the parameters of the models with the direct counting methods gave similar results.
The reconstructed sequences of the hidden states did not oscillate between the different hidden states as in the models based on the EM algorithm. The transition matrix obtained without prior information on the length of the regions allowed to identify long homogeneous regions and to compare them to the C and V regions previously defined.
At this point, we developed models with an unique C region. This C region do not fit a real region but represent an average of all the constant regions. There is no guarantee a priori that the constant regions are grouped together and can be modeled by an unique state. However, the C region introduced in our models allowed to predict all the constant regions with an amazing accuracy.
Tests of the models of EIAV C/V regions
Since our models were able to predict the C and V regions on both deduced aminoacid and nucleotide sequences of EIAV SU, we put them under trial in several directions. First, we checked that the models were not overfitted, keeping in mind that pseudocounts were introduced to limit the overfitting problem. We checked whether the models were not overly specific of the training data, and whether it was possible to make them encompass new data tests. To perform such tests, the models were trained using nucleotide or aminoacid sequences sharing a minimal amount of motifs with the test sequences. For example, we trained the models on virus sequences, which were present at the beginning of the disease induced in horses by EIAV, and we tested them on virus sequences at later stages of the disease [6]. Because of the variations due to viral replication during the time course of the EIAV infection, the training and test sequences displayed 7.8 % (± 1.3) of divergence at the aminoacid level. In particular, the test and training sequences displayed 43.8 % (± 20.2) of divergence in the third V region (V3). Despite this important level of divergence between the training and test sequences, the models correctly predicted the C and V regions, notably V3.
To check that the models were not simply following the order and positions of the V regions along the sequence, we also assembled artificial sequences with a greater number of V regions than in the real ones. For instance, we inserted a copy of 15 aminoacids, taken from V7, into C2. The models which were trained with the fixed EM algorithm on the original sequences, managed to predict perfectly the additional V region of these modified sequences (Figure 2C).
Combined C/V models
Separation of the EIAV C/V regions
The models developed in our study allow us to differentiate the C and V regions of EIAV and to distinguish each of the 8 variable regions. This indicates that the C and V regions have distinct statistical composition and that the 8 variable regions are statistically distinct too. A classical method to quantify the differences between the Markov chains which represent the C and V regions of EIAV, is to consider the relative entropy, also named KullbackLeibler divergence, between these models, see [21–26]. The relative entropy of two Markov chains is given by
where P and Q are the transition matrix of the two Markov chains and π the invariant distribution associated to P. We used a symmetrized form of the relative entropy, defined as
δ(P,Q) = H(PQ) + H(QP).
Symmetrized relative entropy between the C/V regions of EIAV.
δ  C1  C2  C3  C4  C5  C6  C7  C8  C9  C  V  V1  V2  V3  V4  V5  V6  V7  V8 

C1  0  4.40  5.08  4.63  4.65  5.08  4.26  4.70  3.52  2.55  3.70  3.62  2.80  3.67  3.77  3.37  3.70  4.00  3.25 
C2  0  6.25  5.77  5.93  6.38  5.90  4.65  5.37  2.58  4.60  4.46  3.47  4.53  4.72  4.96  4.94  4.72  3.78  
C3  0  6.00  6.62  5.69  5.77  5.35  5.35  2.85  4.86  4.78  4.07  4.51  4.71  4.87  5.18  4.76  4.73  
C4  0  6.36  5.71  5.22  5.06  5.09  2.65  4.95  4.70  3.48  4.85  5.14  5.04  4.13  5.26  4.28  
C5  0  6.86  6.08  6.17  5.00  2.97  4.88  4.81  3.64  4.96  5.35  4.95  5.41  4.71  4.54  
C6  0  6.21  4.70  5.25  3.18  4.70  4.60  3.40  4.75  4.74  4.75  4.67  5.20  3.90  
C7  0  4.92  4.85  2.37  4.71  5.15  3.93  5.16  4.99  4.93  4.63  4.47  4.88  
C8  0  4.34  2.66  4.68  3.77  3.20  4.25  4.11  4.80  4.04  4.50  3.36  
C9  0  2.48  3.84  3.92  3.22  4.16  4.32  4.13  4.84  4.00  3.32  
C  0  3.35  3.64  3.19  3.70  3.78  3.62  3.99  2.96  3.01  
V  0  2.25  2.07  1.91  2.11  2.09  2.21  1.87  2.36  
V1  0  2.41  3.79  3.26  3.07  3.59  3.64  3.57  
V2  0  2.79  2.73  2.71  2.59  2.77  2.34  
V3  0  3.63  3.77  3.60  4.54  3.41  
V4  0  3.57  3.66  4.09  4.03  
V5  0  4.08  3.77  3.69  
V6  0  4.25  3.52  
V7  0  3.83  
V8  0 
To further quantify this separation between the C and V regions, we built an asymptotic statistical test for the empirical transition matrices of two different regions, based on the following considerations. Assuming in general that $\widehat{{q}_{1}}$ and $\widehat{{q}_{2}}$ are empirical transition matrices of the same Markov chain with theoretical transition matrix q, based on two independent sequences of length L of the Markov chain, one can show that LH($\widehat{{q}_{1}}$, $\widehat{{q}_{2}}$) is asymptotically χ^{2}distributed with D(q) degrees of freedom, where D(q) denotes the "dimension" of the Markov chain, that is, D(q) is the number of nonzero coefficients in q minus the number of states [see Additional file 1]. When every transition has positive probability and q has size M, D(q) = M^{2}  M. In particular,
E(H($\widehat{{q}_{1}}$, $\widehat{{q}_{2}}$)) ~ D(q)/L.
In the still more general case when $\widehat{{q}_{1}}$ and $\widehat{{q}_{2}}$ are based on independent sequences of unequal lengthes L_{1} and L_{2} respectively, a similar result holds, namely that ℓ H($\widehat{{q}_{1}}$, $\widehat{{q}_{2}}$) is asymptotically χ^{2}distributed with D(q) degrees of freedom, where ℓ denotes the harmonic mean of L_{1} and L_{2}, defined by the relation
Using the symmetrized entropy δ, one sees that the distribution of $\frac{1}{2}\ell \delta (\widehat{{q}_{1}},\widehat{{q}_{2}})$ is asymptotically χ^{2} with D(q) degrees of freedom, and in particular,
E(δ($\widehat{{q}_{1}}$, $\widehat{{q}_{2}}$)) ~ 2D(q)/ℓ.
Using this result, one can perform χ^{2} tests of equality between the C and V regions of EIAV. This yields pvalues very close to zero. The biggest pvalue is obtained for the two variable regions V1 and V2 and is 4·10^{17}. Since the pvalues are so small, one can conclude that the Markov chains previously defined to model the C and V regions of EIAV do not reflect the same statistical composition in words of amino acids. Hence, each of the 9 constant regions and the 8 variable regions has a specific signature.
Discussion
We report that HMMs are able to predict the C/V segmentations of various lentiviruses, based only on their deduced aminoacid sequences or their nucleotide sequences, with an amazing accuracy and a great robustness.
We would like to stress the fact that our algorithms identify the V regions without any comparison by alignment with known sequences. The models developed in this study are not based on computations of divergences between sequences. Furthermore, the lengths of the regions exhibit great variability, and the numbers of regions themselves may be, and indeed are sometimes, different from one sequence to another. These, and the various tests presented in section Results, prove that the models do not rely on the relative positions of the regions, nor on their lengths, to identify C/V segmentations of the sequences. On the contrary, they have to rely only on some statistical differences between the compositions in words of nucleotides or aminoacids of length 1 + m, where m is the order of the model.
More detailed consequences of the performances of the models are as follows. First, all the C regions can be suitably modeled by a unique state. This proves that they have similar statistical properties. The V regions can be modeled either by one state or by several states. This suggests that V regions share common properties, when compared to C regions, and, at the same time, that each V region has its own statistical profile.
It may be of interest to note that a model, trained on EIAV sequences only, failed to identify the C and V regions of other lentiviruses, and conversely. Hence, the genetic compositions of the env genes of these different lentiviruses are distinct. However, the C and V regions of EIAV, HIV, SIV and SRLV do share some properties which are similar enough, so as to be recognized by a unique HMM, trained on a combined pool of EIAV, HIV, SIV and SRLV SU sequences. This combined model also predicts the C/V segmentation of BIV and FIV, whose sequences were not used to train the model. This supports the conclusion that the statistical compositions in words of nucleotides or aminoacids of the envelope genes of all these lentiviruses share some common features.
Models of order m = 5 on nucleotide sequences, based on the frequencies of words of length 6, predict with an amazing accuracy the C/V segmentations. These words correspond to one or two complete codons. This length is also compatible with the number of nucleotides that are in the neighborhood of the palm of RT during the retrotranscription [27–29]. This suggests that some mechanism of inaccurate nucleotide substitution, possibly due to sequencespecific variations and in interaction with the side chains of the RT protein, might modify the speed and/or the precision of the passage along the portion of the RNA chain which the RT copies.
Conclusion
The constant and variable regions of the lentiviruses EIAV, HIV, SLRV, SIV, BIV, and FIV can be identified by rather crude mathematical models based on HMMs. We attempt at present to extract the nature of the statistical signals which allow to distinguish between these regions. In this spirit, it has been reported that the retroviral G → A hypermutation occurs mainly in specific dinucleotide contexts, like GpG and GpA [30, 31]. Hence, one of our objectives now is to compare to known contexts of mutation the nucleotide words which are, as the present study shows, statistically characteristic of the variable regions of these lentiviruses.
The most interesting contribution of the combined models based on nucleotide or deduced aminoacid sequences of different lentiviruses is the rapid identification of the C and V regions on newly identified lentivirus sequences without the requirement to alignment. This should be especially useful for highly divergent sequences.
HMMs are usually used to identify homogeneous segments in long sequences. In this study, we showed that HMMs are powerful tools able to identify very short segments in sequences of just few hundred nucleotides. We are considering to generalize our method to study small motifs in short sequences.
Methods
Biological data
GenBank accession numbers of the sequences used in this study.
EIAV  AF005104 to AF005151 (except AF005113, AF005136 and AF005145 to AF005148); AF016316; AF298666 to AF298762 (except AF298752 and AF298691 to AF298694); AF429316 to AF429353 

HIV  K03455; AB032740, AB03274; AF133821; AF190127, AF190128; AF197340; AF209205, AF209208; AF219261, AF219272; AF322202 to AF322214; AF411964, AF411965; AF413978, AF413979; AF413987; AF443113 to AF443115; AF457079 to AF457090 (except AF457082 to AF457084, AF457086 and AF457089); AF460972, AF460974; AF484478, AF484493; AF484507 à AF484519 (except AF484508, AF484510, AF484512 and AF484517); AF529572, AF529573; AF530576; AF544007, AF544008; AJ417424 to AJ417431; AY037268 to AY037270; AY037280 to AY037283; AY158533 to AY158535; AY173957, AY173958; AY217545; AY228556, AY228557; AY253305 to AY253322 (except AY253307, AY253309, AY253315 to AY253316 and AY253319); AY255823 to AY255827; AY322184 to AY322191 (except AY322186 and AY322188); AY357571 to AY357576 (except AY357574); AY358069 to AY358073 (except AY358070); AY371155 to AY371163 (except AY371158 to AY371162); AY423908 to AY423928; AY494965 to AY494974 (except AY494967 to AY494968, AY494970 and AY494972); AY505010, AY505011; AY535509 to AY535513; AY563169; AY818641 to AY818643 
SIV  AF075269; AF103818; AF131870; AF188114 to AF188116; AF328295; AF334679; AF382828, AF382829; AF447763; AY033233; AY159321, AY159322; AY169968; AY221508 to AY221513; AY290709 to AY290716; AY523865 to AY523867; AY587015; AY588946; AY599198 to AY599201; AY611488; L20008, L20009; L20098, L20099; L40990; M29975; M33262; M58410; M66437; M83293; U04005; U10897 to U10898; U25712 to U25715; U25744, U25745; U58991; U72748 
SRLV  A15114; AF015180; AF156858 to AF156877; AF338227; AF474005 to AF474007; AF479638; AJ400718 to AJ400721; AY039765 to AY039784; L06906; M31646; M33677; M34193; M60609, M60610; M60855; S51392; S55323; U35795 to U35804 (except U35797, U35802 and U35803); U51910 
BIV  L43126 to L43132; M32690; NC_001413; L04972; U80989 to U80991 
FIV  M25381; M36968; L00608; M59418; X57001 to X57002; M73964 to M73965; X60725; L06725; X69494 to X69502 (except X69495, X69500 and X69501) 
Training set: 94 sequences. Test set: 93 sequences.
According to the regions described in [6], we considered 8 variable regions (V1 to V8) and 9 constant regions (C1 to C9).

HIV: 155 HIV1 sequences. The panel is composed of the HIV1 HXB2 sequence and representative sequences from the following subtypes: A (21 sequences), B (27 sequences), C (26 sequences), D (18 sequences), E (19 sequences), F (3 sequences), G (21 sequences), H (2 sequences), and 17 sequences of recombinant forms.
Training set: 78 sequences. Test set: 77 sequences.
Variable regions V1 to V5 are as defined in [7]. However, V1 and V2 are considered as a unique variable region V1/V2, since these variable regions are separated by a small constant region composed of only a few nucleotides.

SIV: 61 sequences. Training set: 45 sequences. Test set: 15 sequences.
Variable regions V1 to V5 are as defined in [5].

SRLV: 68 sequences. Training set: 51 sequences. Test set: 17 sequences.
Variable regions V1 to V5 are as defined in [8].

BIV: 13 sequences. Test set: 13 sequences.
We compared the predicted regions with the variable regions V1 to V6 previously defined in [10].

FIV: 16 sequences. Test set: 16 sequences.
We compared the predicted regions with the variable regions V1 to V5 previously defined in [11].
Hidden Markov models
We recalled in the introduction that HMMs involve pairs of random processes, called respectively the hidden process and the observed process. In our context, the hidden process (S_{ i })_{1 ≤ i ≤ L}describes the succession of homogeneous regions along a sequence of length L. For every i, S_{ i }belongs to a given finite set of size N and is called the hidden state at position i. The observed process (X_{ i })_{1 ≤ i ≤ L}describes the nucleotide sequence or the deduced aminoacid sequence. For every i, X_{ i }belongs to a given finite alphabet $\mathcal{X}$ of size M and is called the observation at position i. For instance, M := 4 and $\mathcal{X}$ : = {A, C, G, T} for nucleotide sequences, and M := 20 for deduced aminoacid sequences.
We use HMMs of type M1Mm, hence the hidden process is a first order Markov chain. That is, the value S_{ i }at position i depends probabilistically on the value S_{i  1}at position i  1. The transition matrix T is defined as
T(s's) := P(S_{ i }= s'S_{i1}= s),
for every states s and s', that is, T(s's) denotes the probability that S_{ i }= s', conditionally on the fact that S_{i  1}= s. In turn, conditionally on the state process, the observed process is an inhomogeneous Markov chain of order m whose transition probabilities at position i depend only on S_{ i }. The emission matrix B is defined as
B(x s,x_{1}, ..., x_{ m }) := P(X_{ i }= x  X_{i  1}= x_{1},..., X_{im}= x_{ m }, S_{ i }= s),
for every state s and every observations x, x_{1}, ..., x_{ m }. In words, the state at a given position depends on the state at the previous position, and the observation at a given position depends on the state at the same position and on the m previous observations.
Hence, the full model is specified by the pair of matrices (T, B) and by some initial distributions.
Parameter estimation
The estimation of the best model (T, B) for a given training set of sequences is usually based on maximum likelihood methods. Assume first that the segmentation of the observed sequences is available, that is, that one knows the state sequences. Then, the parameters of the model can be estimated with direct counting methods. For every states s and s', one sets
where N(s), respectively N(ss'), denotes the number of times the letter s, respectively the word ss', appears in the state sequence, that is,
Likewise, for every observations x, x_{1}, ..., x_{ m }, and every state s, one sets
with
Here N(x_{ m }... x_{1}zs) is the number of times the word x_{ m }... x_{1}z appears in the observation sequence while the state is s at the position of the observation x, that is,
As is well known, maximum likelihood estimators are sensitive to overfitting. To avoid such problems, we added constant pseudocounts n_{0} to every N(s), N(ss') and N(x_{ m }... x_{1}zs), equal to n_{0} := 1.
Reconstruction algorithms
When the segmentation of the training sequences is not available, the maximum likelihood estimators ($\widehat{T}$, $\widehat{B}$) of (T, B) cannot be directly computed. But there exists several algorithms which estimate iteratively the parameters of the models with no foreknowledge of either the observation process or the state process. The most classical one is the expectationmaximization (EM) algorithm, introduced by [36]. In the context of hidden Markov chains, this algorithm is known as the BaumWelch algorithm, see [13, 37] for a detailed description of the algorithm, and [12]. To compute maximum likelihood estimates of the parameters, this algorithm alternates Esteps and Msteps until convergence. During each Estep, the algorithm estimates the missing data (the hidden states sequence), computing the most likely state sequence with respect to the current value of the parameters, obtained through the preceding Mstep. During each Mstep, the algorithm maximizes the transition and emission probabilities, using the state sequence computed during the preceding Estep. There is no guarantee that the EM algorithm should produce a sequence (T_{ n }, B_{ n })_{n ≥ 0}of models which converges to ($\widehat{T}$, $\widehat{B}$). Indeed, starting from an unspecified initial point (T_{0}, B_{0}), the algorithm can get stuck in one of many local maxima of the likelihood. But there exists a neighborhood of ($\widehat{T}$, $\widehat{B}$), such that, for any (T_{0}, B_{0}) in this neighborhood, (T_{ n }, B_{ n })_{n ≥ 0}indeed converges to ($\widehat{T}$, $\widehat{B}$) ([38, 39]). To introduce some information about the composition of the different regions, we also define and use a new algorithm based on the EM algorithm and on direct counting methods. The details of this new algorithm are as follows. The emission matrix B, corresponding to the transition probabilities between observations for each state, is defined by counting on training sequences. Then one estimates iteratively the state transition probabilities of the T matrix with the EM algorithm, keeping every emission probabilities at their calculated value. The Mstep of the EM algorithm is modified, to omit the usual maximization of the emission probabilities. Then, the Estep and the maximization of the transition probabilities are performed as in the classical EM algorithm. We call this new algorithm fixed EM algorithm (which stands for EM algorithm with fixed emission probabilities). In details, the fixed EM algorithm produces a sequence (T_{ n }, B_{ n })_{n ≥ 0}of models as follows.
Step Initiation
The transition probabilities T_{0} are initialized using random values. The emission matrix B_{0} is defined by counting on training sequences as follows:
with the same notations than in the section "Parameter estimation".
Step Estimation (E)
Computation of the probability P_{k, ℓ}of every successives states k and ℓ in S, under the current value (T_{ n }, B_{ n }).
P_{k,ℓ}= P(S_{ i }= k, S_{i+1}= ℓx_{1}, ..., x_{ L }, (T_{ n }, B_{ n })).
This probability can be computed using the forward and backward variables f_{ k }(i) and b_{ k }(i) defined by:
f_{ k }(i) = P(x_{1}, ..., x_{ i }, S_{ i }= k),
and
b_{ k }(i) = P(x_{i+1}, ..., x_{ n } S_{ i }= k, x_{im+1}, ..., x_{ i }).
We have:
Step Maximization (M)
Computation of (T_{n+1}, B_{n+1}), through the formulas
where
and
B_{n+1}= B_{0}.
Step End
The steps E and M are executed alternatively until convergence.
The fixed EM algorithm converges to the maximum likelihood estimators ($\tilde{T}$, $\tilde{B}$) conditioned by the emission matrix B. The model ($\tilde{T}$, $\tilde{B}$) yields a lower likelihood than the model ($\widehat{T}$, $\widehat{B}$) obtained with the EM algorithm. Experimentally, on EIAV sequences, we observe that the convergence of fixed EM occurs 10 times faster than the convergence of the EM algorithm. We defined the fixed EM algorithm to introduce some information about the number N of types of regions and the statistical composition in words of nucleotides or aminoacids of these regions. On the contrary, we introduced no information about the order or the position of the regions along the sequence.
In both EM and fixed EM algorithms, to reconstruct the hidden states sequence and to identify the predicted C and V regions, one determines the sequence of the most probable hidden states, that is, one computes at each position i of the sequence the likelihood of the different hidden states (S_{ i }= s) conditionally on the observed sequence and one selects the state with the highest likelihood. The likelihood of the hidden states for each position is computed using the classical forwardbackward algorithm, described by [40].
Declarations
Acknowledgements
ABQ is the recipient of an INRA fellowship.
Authors’ Affiliations
References
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