Reconstruction of ancestral protein sequences and its applications
- Wei Cai†^{2},
- Jimin Pei†^{2} and
- Nick V Grishin^{1, 2}Email author
DOI: 10.1186/1471-2148-4-33
© Cai et al; licensee BioMed Central Ltd. 2004
Received: 04 June 2004
Accepted: 17 September 2004
Published: 17 September 2004
Abstract
Background
Modern-day proteins were selected during long evolutionary history as descendants of ancient life forms. In silico reconstruction of such ancestral protein sequences facilitates our understanding of evolutionary processes, protein classification and biological function. Additionally, reconstructed ancestral protein sequences could serve to fill in sequence space thus aiding remote homology inference.
Results
We developed ANCESCON, a package for distance-based phylogenetic inference and reconstruction of ancestral protein sequences that takes into account the observed variation of evolutionary rates between positions that more precisely describes the evolution of protein families. To improve the accuracy of evolutionary distance estimation and ancestral sequence reconstruction, two approaches are proposed to estimate position-specific evolutionary rates. Comparisons show that at large evolutionary distances our method gives more accurate ancestral sequence reconstruction than PAML, PHYLIP and PAUP*. We apply the reconstructed ancestral sequences to homology inference and functional site prediction. We show that the usage of hypothetical ancestors together with the present day sequences improves profile-based sequence similarity searches; and that ancestral sequence reconstruction methods can be used to predict positions with functional specificity.
Conclusions
As a computational tool to reconstruct ancestral protein sequences from a given multiple sequence alignment, ANCESCON shows high accuracy in tests and helps detection of remote homologs and prediction of functional sites. ANCESCON is freely available for non-commercial use. Pre-compiled versions for several platforms can be downloaded from ftp://iole.swmed.edu/pub/ANCESCON/.
Background
Present-day protein sequences can be used to reconstruct ancestral sequences based on a model of sequence evolution. Such knowledge about ancestral sequences is helpful for understanding the evolutionary processes as well as the functional aspects of a protein family. Existing methods of ancestral sequence reconstruction can be divided into two main categories: Maximum Parsimony (MP) methods [1, 2] and Maximum Likelihood (ML) methods [3–5]. MP methods do not take into account biased substitution patterns between amino acids or different tree branch lengths, and cannot distinguish those equally parsimonious reconstructions [3]. ML methods do not have these limitations and generally give more reliable results than the MP methods [6]. Yang et al. [3] first developed a ML method for ancestral sequence reconstruction. Yang [7] also made a distinction between "joint" reconstruction and "marginal" reconstruction. Joint reconstruction methods intend to find the most likely set of amino acids for all internal nodes at a site, which yields the maximum joint likelihood of the tree [5]. Marginal reconstruction compares the probabilities of different amino acids at an internal node at a site and selects the amino acid that yields the maximum likelihood for the tree at that site. Marginal reconstruction can also compute probabilities of all other amino acids for that node [4]. Koshi and Goldstein [4] developed a fast dynamic programming algorithm for marginal reconstruction in the framework of Bayesian statistics, while Pupko et al. [5] proposed a fast algorithm for joint reconstruction. The computational complexities for both algorithms scale linearly with the number of sequences. Both marginal and joint reconstruction algorithms are implemented in our program.
All reconstruction methods require a phylogenetic tree inferred from a given alignment. The quality of the tree is crucial for the reliability of reconstruction. A number of methods exist for phylogenetic inference, such as maximum likelihood [8], distance-based [9] and parsimony [1]. Distance-based methods have the advantage of being simple and are able to handle a large set of sequences. They require evolutionary distances estimated for all the sequence pairs. The most common method to infer phylogeny from distances is based on the neighbor-joining algorithm [9]. Bruno et al. [10] introduced a distance-based phylogeny reconstruction method called "Weighbor", i.e. "weighted neighbor joining", which takes into account the fact that errors in distance estimates are larger for longer distances. Giving similar results, Weighbor is much faster than ML phylogeny reconstruction. It is also better than other methods such as BIONJ [11] and parsimony [1], in aspects of "long branches attract" and "long branch distracts" problems [10]. Weighbor is used in our program for phylogenetic inference.
Overwhelming evidence exists for substitution rate variation across sites [12–15]. For a protein family, rate heterogeneity reflects the selective pressure imposed by folding, stability and function. Gamma distribution is widely used to model the rate variation among sites [13, 16, 17] because of its simplicity. Nielsen [18] suggested a method for site-by-site estimation of rate factors by a Maximum Likelihood approach. Rate variation among sites has not been taken into account in the early work of ML reconstruction of ancestral sequences [4, 5]. Recently, Pupko et al. [19] introduced rate variation into joint reconstruction by a branch-and-bound algorithm, assuming a gamma distribution of rates among sites. In our package, two methods are proposed to estimate a rate factor for each site. The first one is based on our observation that the substitution rate at a site is correlated with the conservation of the site. The more conserved the site is in a multiple sequence alignment, the smaller its substitution rate is. This empirical method, the result of which we call Alignment-Based rate factors or α_{ AB }, relies only on a multiple sequence alignment and a general model of amino acid exchange. The other one is a maximum likelihood method (α_{ ML }), which requires a tree. In our implementation, we incorporate α_{ AB }or α_{ ML }in the joint and marginal reconstruction algorithms [4, 5]. α_{ AB }is also used in the Maximum Likelihood estimation of evolutionary distances [20] for tree inference.
We implement a method of evolutionary simulation that introduces site-specific rate variations in a natural way by imposing structural and functional constraints [21]. We show by simulations that the reconstruction methods can give reasonable results and that the problem of evolutionary distance underestimation [22] is alleviated by considering rate variation across sites.
Background (or equilibrium) amino acid frequencies (π) are usually estimated from the target set of sequences or from large databases of protein families. Background amino acid frequencies estimated from a small dataset tend to have bias, while amino acid frequencies from large databases may not be suitable for the specific protein family under analysis. Here, we propose a ML method to optimize the amino acid frequency vector π. The optimized π vector can give significant improvement over the likelihood of a alignment.
Information obtained from ancestral sequence reconstruction is used for two applications: homology detection and prediction of functional sites. For homology detection, ancestral sequences represent an enlargement of the sequence space around native sequences. We demonstrate that adding reconstructed ancestral sequences to a native alignment improves the detection of homologs in database searches.
A number of methods have been developed to predict functional sites from amino acid sequences [23, 24]. One simple way to infer functional sites is by positional conservation of a multiple sequence alignment [25]. Lichtarge et al. [26] proposed a method called evolutionary trace to predict functional sites by analyzing the conservation of sequence subgroups. Functional divergence during the evolutionary process can be reflected in the variation of amino acid usage across different functional subgroups. We propose a new approach that uses information from ancestral sequence reconstruction to identify sites that are well conserved within individual sub-trees but exhibit variability among different sub-trees. By several examples, we show that these sites frequently contribute to the functional specificity of a protein family.
Results and discussion
We developed a package (ANCESCON) to reconstruct ancestral protein sequences considering rate variation among sites. Rate factors can be estimated either by an empirical method or by a maximum likelihood method. Consideration of rate variation among sites not only improves evolutionary distance estimation, but also gives more accurate ancestral sequence reconstruction. Ancestral sequences are used to improve profile-based sequence similarity searches. We also propose a new approach to predict positions with functional specificity based on the reconstruction of ancestral sequences.
Observed α, Alignment Based Rate Factor α (α_{ AB }) and Rate Factor α estimated by Maximum Likelihood (α_{ ML })
Evolutionary simulations based on a Z-score model introduce rate variation across sites in a natural way by incorporating structural and functional constraints specific for a protein family [21]. The simulation procedure is a Monte Carlo simulation of the amino acid substitution process. The fixation of substitutions is dictated by a simple scoring function, which is derived from the template structure and an alignment of its homologs. The number of substitutions occurring at each site can be recorded during the simulation process and the observed α at a site equals the number of recorded substitutions at that site divided by the average substitution number for all sites. To reduce sampling variance, an average observed α vector is calculated from 100 simulations.
For the alignment consisting of all the leaf node sequences generated by the simulation process, an α_{ AB }vector was calculated according to equation (11) (for details see Methods). An average α_{ AB }vector was derived from 100 simulations. Correlation coefficient between the average α_{ AB }vector and the average observed α vector was high (data not shown). However, we found that for large observed α values, the corresponding α_{ AB }values were smaller. A constant β was introduced to correct this underestimation in equation (11).
Here, α_{ i }is Alignment-Based rate factor at site i. K is the number of sites in a given alignment. C_{ i }is the value assigned to site i (for details see Methods).
Difference of logarithm likelihood and CPU time when using different α vectors
α = 1.0 | α _{ AB } | α _{ ML } | |||||
---|---|---|---|---|---|---|---|
Δl | P* | Δl | P* | ||||
Logarithm Likelihood | -5324.56 | -5087.72 | 236.84 | <0.0001 | -4987.27 | 337.29 | <0.0001 |
CPU Time (s)^{+} | 213 | 213 | 359 |
Rate variation across sites can be modeled by assuming that the rate factors follow a certain type of statistical distribution. Gamma distribution [13, 27] and its discrete approximations [28] are frequently used for DNA or protein sequences. Rate variation for a protein family reflects different selective pressure at different sites to maintain structure and function. Fewer substitutions are expected to occur in more conserved sites. This hypothesis has prompted us to estimate rate factors (α_{ AB }) based on sequence conservation in an empirical way. The α_{ AB }is compared and calibrated using the observed α as standards. Our method of estimating α_{ ML }is similar to the one proposed by Nielson [18]. One problem with site-by-site rate factor estimation is the small sample size at each site, especially with a small alignment. We have used α_{ AB }to eliminate outliers with very large α_{ ML }estimates (for details see Methods).
Site-specific rate factors improve distance estimation
Optimization of equilibrium frequencies
Difference of logarithm likelihood and CPU time with and without optimization of π vector
α_{ AB }& Calculated π | α_{ AB }& Optimized π | Δl | P* | |
---|---|---|---|---|
Logarithm Likelihood | -5087.72 | -5055.97 | 31.75 | <0.0001 |
CPU Time (s)^{+} | 213 | 14902 |
Optimization of the π vector is time consuming. The running time for reconstruction with or without optimizing π vector is 14,902 seconds and 213 seconds for SH2 alignment (44 sequences), respectively, on a Dell PowerEdge 8450 server (CPU 700MHz, RAM 8G) (Table 2). In our program, the default π vector is calculated from the alignment while the user has the option to optimize the π vector for ancestral sequence reconstruction.
Testing reconstruction
For the second simulation method, we introduced rate heterogeneity across sites with structural and functional constraints [21]. For the same tree, the accuracy of reconstruction was about 90%. Sites with larger substitution rates are expected to have less reliable reconstructions. Figure 4b shows the relationship between the average α_{ AB }and the fraction of individual predictions that are correct according to the "reconstructed amino acid". Sites with incorrect "reconstructed amino acids" all have large α_{ AB }values. These values reflect the difficulty of reconstructing sites with large numbers of substitutions. The probabilities of the "reconstructed amino acids" are all small for sites with incorrect reconstructions (less than 0.15), suggesting that the information content of the reconstruction is low.
The second simulation method was also used to test ANCESCON along with the reconstruction programs from PAML [30], PHYLIP [31] and PAUP* [32]. All tree topologies used in reconstruction tests were inferred from real alignments. All original root sequences were taken from PDB database [33]. We had three different types of alignment testing sets. The first testing set used the same tree topology but different root sequences to generate 100 alignments (for details see Methods). The second testing set used the same root sequence but different tree topologies. The third testing set randomly selected a root sequence and a tree topology to generate 100 alignments. After 100 alignments were generated, we reconstructed the root sequence for each alignment and found the consensus root sequence for the 100 reconstructed root sequences. Finally, the consensus root sequence was compared with the original root sequence to calculate the reconstruction accuracy, i.e. the fraction of correctly reconstructed sites for the root sequence. In addition, for the third test, the paired t-test was used to calculate the one-tail probability between ANCESCON and other three methods. In order to make different tree topologies comparable, those trees were scaled to make the average distance from root to all leaf nodes (d_{ a }) the same for all trees and equal to the tree of pii1 (a signal transduction protein) (d_{ a }= 4.23). If d_{ a }was too small (e.g. 0.5), the reconstruction accuracy was always close to 1 for all reconstruction methods used. The value d_{ a }= 4.23 was large enough to generate diverse sequences to differentiate 4 different ancestral sequence reconstruction methods.
For ANCESCON we had 3 different parameter settings, which included site-specific rate factors estimated by maximum likelihood method (α_{ ML }), Alignment-Based rate factors (α_{ AB }) and no rate factors (equal rates among sites). Different parameters were also used for the reconstruction programs from PAML and PHYLIP to find their best reconstructions. For PAML, reconstruction was tested with parameter α (rate factor) estimated from alignment and without α. For PHYLIP, 4 different parameter settings were tried, which were combinations of with/without α estimated from alignment by PAML and with/without branch length dwelling in input tree topology. For PAUP*, default settings were used.
Ancestral sequence reconstruction accuracy by different programs
Root Seq. | Tree | Leaf Node Num. | Methods | |||||||||
---|---|---|---|---|---|---|---|---|---|---|---|---|
ANCESCON | PAML | PHYLIP $ | PAUP* | |||||||||
α _{ ML } | α _{ AB } | -α | +α | -α | +L +α | -L +α | +L -α | -L -α | ||||
1em2 | pii1 | 25 | 0.45 | 0.32 | 0.35 | 0.41 | 0.37 | 0.29 | 0.27 | 0.21 | 0.29 | 0.26 |
1g9o | pii1 | 25 | 0.56 | 0.46 | 0.47 | 0.53 | 0.53 | 0.51 | 0.54 | 0.40 | 0.51 | 0.47 |
1rgg | pii1 | 25 | 0.60 | 0.42 | 0.47 | 0.60 | 0.62 | 0.47 | 0.58 | 0.32 | 0.56 | 0.47 |
1sgt | pii1 | 25 | 0.38 | 0.34 | 0.33 | 0.33 | 0.32 | 0.32 | 0.33 | 0.27 | 0.33 | 0.32 |
1zm2 | pii1 | 25 | 0.33 | 0.29 | 0.3 | 0.28 | 0.25 | 0.21 | 0.25 | 0.21 | 0.27 | 0.16 |
2a8v | pii1 | 25 | 0.62 | 0.45 | 0.42 | 0.56 | 0.55 | 0.44 | 0.46 | 0.28 | 0.50 | 0.36 |
2ctb | pii1 | 25 | 0.53 | 0.40 | 0.39 | 0.41 | 0.38 | 0.24 | 0.24 | 0.21 | 0.29 | 0.22 |
Average accuracy | 0.496 | 0.383 | 0.390 | 0.446 | 0.431 | 0.354 | 0.381 | 0.271 | 0.393 | 0.323 | ||
2ctb | gef | 27 | 0.54 | 0.37 | 0.38 | 0.35 | 0.35 | 0.29 | 0.17 | 0.24 | 0.22 | 0.22 |
2ctb | LacI | 54 | 0.66 | 0.64 | 0.57 | 0.44 | 0.37 | 0.49 | 0.35 | 0.42 | 0.33 | 0.34 |
2ctb | pdz | 39 | 0.54 | 0.41 | 0.42 | 0.44 | 0.39 | 0.22 | 0.34 | 0.18 | 0.32 | 0.22 |
2ctb | ph | 30 | 0.79 | 0.74 | 0.75 | 0.53 | 0.55 | 0.45 | 0.25 | 0.43 | 0.37 | 0.32 |
2ctb | pii1 | 25 | 0.53 | 0.40 | 0.39 | 0.41 | 0.38 | 0.24 | 0.24 | 0.21 | 0.29 | 0.22 |
2ctb | ptb | 29 | 0.58 | 0.39 | 0.43 | 0.39 | 0.38 | 0.29 | 0.23 | 0.26 | 0.24 | 0.23 |
2ctb | sh2 | 34 | 0.61 | 0.42 | 0.40 | 0.43 | 0.40 | 0.30 | 0.22 | 0.20 | 0.27 | 0.22 |
2ctb | sh3 | 43 | 0.83 | 0.82 | 0.80 | 0.62 | 0.55 | 0.69 | 0.45 | 0.66 | 0.46 | 0.54 |
2ctb | GST | 140 | 0.76 | 0.73 | 0.73 | @ | @ | # | # | 0.47 | 0.38 | 0.33 |
Average accuracy^{&} | 0.635 | 0.524 | 0.518 | 0.451 | 0.421 | 0.371 | 0.281 | 0.325 | 0.313 | 0.289 | ||
1em2 | pdz | 39 | 0.45 | 0.35 | 0.36 | 0.44 | 0.44 | 0.29 | 0.43 | 0.23 | 0.4 | 0.24 |
1g9o | pii1 | 25 | 0.56 | 0.46 | 0.47 | 0.53 | 0.53 | 0.51 | 0.54 | 0.40 | 0.51 | 0.47 |
1rgg | sh2 | 34 | 0.64 | 0.48 | 0.46 | 0.61 | 0.61 | 0.56 | 0.59 | 0.34 | 0.6 | 0.41 |
1sgt | gef | 27 | 0.49 | 0.39 | 0.40 | 0.48 | 0.44 | 0.42 | 0.44 | 0.36 | 0.45 | 0.41 |
1zm2 | ptb | 29 | 0.66 | 0.47 | 0.48 | 0.57 | 0.57 | 0.53 | 0.51 | 0.32 | 0.52 | 0.41 |
2a8v | ph | 30 | 0.81 | 0.78 | 0.81 | 0.71 | 0.74 | 0.60 | 0.61 | 0.50 | 0.65 | 0.50 |
2ctb | LacI | 54 | 0.66 | 0.64 | 0.57 | 0.44 | 0.37 | 0.49 | 0.35 | 0.42 | 0.33 | 0.34 |
Average accuracy | 0.610 | 0.510 | 0.507 | 0.540 | 0.529 | 0.486 | 0.496 | 0.367 | 0.494 | 0.397 | ||
Probability^{Δ} | 0.0026 | 0.0023 | 0.0248 | 0.0328 | 0.0007 | 0.0168 | 0.0001 | 0.0143 | 0.0005 |
Ancestral sequences used in homology detection
Thirty-eight OB (Oligonucleotide/oligosaccharide binding)-fold [34] proteins and ten other alignments (adenylyl kinase, gef, globin, pdz, ph, ptb, ras, sh2, sh3 and subtilase) from the Pfam database (version 7.3) [29] were chosen to perform homology detection tests.
Given an alignment with N sequences, we had four different methods, "BEST", "SECOND BEST", "SHUFFLE" and "RANDOM", to generate another N-1 sequences (for details see Methods). For each combined alignment (2N-1 sequences), PSI-BLAST [35] searches were performed starting from each sequence and seeded with the combined alignment (-B option in the program BLASTPGP, e-value cutoff 0.01), and all found hits were pooled together.
The benchmark experiment was PSI-BLAST seeded with the native alignment (N sequences). For each type of the four combined alignments, we checked hits not found by the native alignments. New hits were verified to be true positives or false positives by running PSI-BLAST or HMMER [36], followed by manual inspections.
Homology detection results of OB-fold structures using reconstructed ancestral sequences
SCOP Superfamily/family | PDB structure | New homologs | NCBI annotation |
---|---|---|---|
Nucleic acid-binding proteins/ Anticodon-binding domain | 1b7yB, 39–151 | N/A | - |
1b8aA, 1–102 | N/A | - | |
1bbuA, 64–151 | 13431467 | DNA polymerase II small subunit | |
15598836 | DNA polymerase III, alpha chain | ||
1c0aA, 1–106 | 11261591 | DNA polymerase III, alpha chain | |
11499379 | conserved hypothetical protein | ||
1169392 | DNA polymerase III alpha subunit | ||
118794 | DNA polymerase III alpha subunit | ||
13620707 | putative DNA polymerase III, alpha chain | ||
14194684 | DNA polymerase III alpha subunit | ||
14194702 | DNA polymerase III alpha subunit | ||
14195653 | DNA polymerase III alpha subunit | ||
14195659 | DNA polymerase III alpha subunit | ||
15594924 | DNA polymerase III, subunit alpha | ||
15598836 | DNA polymerase III, alpha chain | ||
15601899 | DnaE | ||
15642243 | DNA polymerase III, alpha subunit | ||
15669005 | M. jannaschii predicted coding region MJ0818 | ||
15679404 | DNA polymerase delta small subunit | ||
3914611 | ATP-dependent DNA helicase recG | ||
1cuk, 1–64 | N/A | - | |
1e1oA, 64–148 | 11261591 | DNA polymerase III, alpha chain XF0204 | |
14194684 | DNA polymerase III alpha subunit | ||
1fguA, 181–298 | 15219507 | hypothetical protein | |
15230563 | putative protein | ||
15790309 | Vng1255c from Halobacterium sp. | ||
6166145 | DNA polymerase III alpha subunit | ||
8778702 | T1N15.20 | ||
1fl0A | 10957481 | hypothetical protein | |
1g51A, 1–104 | 14520587 | hypothetical protein | |
14591565 | hypothetical protein | ||
15595886 | hypothetical protein | ||
3914638 | ATP-dependent DNA helicase recG | ||
1otcB, 36–126 | N/A | - | |
1quqA, 62–152 | 15387767 | probable replication protein a 28 Kd subunit | |
1qvcA, 1–114 | N/A | - | |
Nucleic acid-binding proteins/Cold shock DNA-binding domain like | 1a62, 48–125 | N/A | - |
1ah9 | N/A | - | |
1bkb, 75–139 | 15790688 | translation initiation factor eIF-5A; Eif5a | |
1c9oA | 6014735 | Cold shock protein CspSt | |
1csp | N/A | - | |
1d7qA | N/A | - | |
1mjc | N/A | - | |
1rl2 | N/A | - | |
1sro | 15671445 | N utilization substance protein A | |
15794781 | N utilisation substance protein A | ||
15803711 | transcription pausing; L factor | ||
2eifA, 73–132 | N/A | - | |
Nucleic acid-binding proteins/DNA ligase, mRNA capping enzyme, domain2 | 1a0i, 241–349 | N/A | - |
1dgsA, 315–400 | N/A | - | |
1ckmA, 238–302 | N/A | - | |
1fviA, 190–293 | N/A | - | |
Nucleic acid-binding proteins/Phage ssDNA-binding proteins | 1gpc | N/A | - |
1gvp | N/A | - | |
1pfs | N/A | - | |
Nucleic acid-binding proteins/RNA polymerase subunit RBP8 | 1a1d | N/A | - |
Staphylococcal nuclease/Staphylococcal nuclease | 1eyd | 13422779 | aldose 1-epimerase * |
Bacterial enterotoxins/Bacterial AB5 toxins, B units | 1c4qA | N/A | - |
1prtF | N/A | - | |
Bacterial enterotoxins/Superantigen toxins | 1an8, 19–94 | N/A | - |
TIMP-like/Tissue inhibitor of metalloproteases | 1ueaB, 14–106 | N/A | - |
Inorganic pyrophosphatase/ Inorganic pyrophosphatase | 2prd | N/A | - |
MOP-like/BiMOP, duplicated molybdate-binding domain | 1b9mA, 127–262 | 10639288 | probable ATP-binding protein |
10955070 | AgtA | ||
1175513 | Putative ferric transport ATP-binding protein afuC | ||
15598450 | probable ATP-binding component of ABC transporter | ||
3978166 | ATPase FbpC | ||
4895001 | glucose ABC transporter ATPase * | ||
Histidine kinase CheA, C-terminal domain/ Histidine kinase CheA, C-terminal domain | 1b3qA, 540–671 | N/A | - |
Prediction of functional sites
Ten well-studied protein families (adenylyl kinase, gef, globin, pdz, ph, ptb, ras, sh2, sh3 and subtilase) from the Pfam database (version 7.3) [29] were selected to test the prediction of functional sites. To define functional sites, we considered residues falling within 5Å of any ligand to be functionally important (i.e. AP5 for adenylyl kinase). As a simple quantification of prediction accuracy, we counted the number of predictions that lie within 5Å from the ligands and consider these sites to be true positives.
Comparison of the true hits among the top 10 predicted sites for ANCESCON, evolutionary trace (ET), simple conservation (SC), and conservation difference (CD) methods
Protein Family | PDB ID^{#} | Ligand/ substrate | Number of sites | * | ** | *** | ANCESCON | ET | SC | CD |
---|---|---|---|---|---|---|---|---|---|---|
adkinase | 1aky | AP5 | 188 | 42 | 20 | 18 | 3 | 9.5 | 9.1 | 8 |
gef | 1bkd | H-Ras | 245 | 47 | 4 | 0 | 3 | 3 | 3 | 2 |
globin | 1a6g | HEM | 147 | 21 | 1 | 1 | 2 | 5.5 | 6 | 6 |
pdz | 1be9 | + | 81 | 15 | 2 | 1 | 6 | 4 | 4 | 2 |
ph | 1mai | I3P | 109 | 11 | 2 | 0 | 2 | 2 | 3 | 2 |
ptb | 1shc | PTR | 157 | 27 | 2 | 1 | 6 | 5 | 5 | 9 |
ras | 821p | GTN | 185 | 29 | 10 | 9 | 2 | 5.6 | 8.7 | 5 |
sh2 | 1a09 | ACE | 83 | 17 | 2 | 1 | 3 | 5 | 4 | 4 |
sh3 | 1nlo | ACE | 57 | 9 | 1 | 1 | 2 | 5 | 4 | 0 |
subtilase | 1av7 | SBL | 278 | 22 | 8 | 4 | 5 | 4.6 | 3.8 | 4 |
Conclusions
We developed a package (ANCESCON) to reconstruct ancestral protein sequences that takes into account the variation of substitution rates among sites. Two methods were proposed to estimate site-specific evolutionary rates (α), namely Alignment-Based rate factor (α_{ AB }) and rate factor α estimated by maximum likelihood (α_{ ML }). Consideration of rate variation among sites can alleviate the underestimation of evolutionary distances. Accuracy of ancestral sequence reconstruction by our method is higher than that of PAML, PHYLIP and PAUP* when the given alignment contains more diverse sequences. We show that reconstructed ancestral sequences help to improve detection of distant homologs and prediction of functional sites with specificity.
Methods
Transition probability and likelihood calculations
For all models discussed in this paper, we assume all sites in an alignment evolve independently and according to a homogeneous, stationary and time reversible Markov process. The probability of an amino acid i to be replaced by amino acid j after a time interval t is P_{ ij }(t). The transition probability matrix of 20 amino acids is written as P(t), which can be calculated as
P(t) = exp(Q t) (2)
Here, Q is the rate matrix. The non-diagonal elements q_{ ij }are the instantaneous rates of change from amino acid i to amino acid j and diagonal elements q_{ ii }are such that each matrix row sums up to 0. Q can be calculated by:
Q = S* diag(π) (3)
S is the matrix of amino acid exchangeability parameters [39]. π_{ i }is the equilibrium frequency for amino acid i. Time reversibility implies that S is a symmetric matrix. In our program, the S matrix is taken from Whelan and Goldman [39] and the default π vector is estimated from the given alignment.
Q can be decomposed into eigenvalues (λ_{ i }) and eigenvectors (u_{ i }).
U = (u_{1}, ..., u_{20}) (5)
P_{ ij }(t) can be calculated using the following equation,
Considering that each site i has a rate factor α_{ i }[13, 18], we have:
t in equation (6) can be expressed as:
t = α·d (9)
d is the evolutionary distance and α is rate factor. The following restriction on the vector α holds:
Here, K is the number of sites.
Alignment-Based Rate Factor α (α_{ AB }) and Rate factor α estimated by Maximum Likelihood (α_{ ML })
Our program supports two methods to estimate a rate factor for each site: Alignment-Based rate factor α (α_{ AB }) and Maximum Likelihood-estimated rate factor α (α_{ ML }).
The estimation of α_{ AB }is empirical and based on the observation that the substitution rate at a site is correlated with the conservation of the site, which, in turn, is correlated with the average transition probability among the amino acids at that site. Conserved sites are dominated by highly similar amino acids and thus have high average transition probabilities among the amino acids. The algorithm to calculate α_{ AB }is as follows:
1. Set t equal to 1.0 and use equation (6) to calculate a transition probability matrix P for 20 amino acids. Equation, , is used to compute a symmetric matrix P'.
3.For invariant sites, C_{ i }is set to 0 to make it consistent with the Maximum Likelihood estimation.
4. Equation (11) is used to calculate α_{ AB }, so that equation (10) holds.
If an evolutionary tree is assumed for the alignment, we can estimate the α_{ ML }factors by maximizing the likelihood (equation (8)) for each site:
If some sites are highly variable, the α_{ ML }at those sites can be very large, as has been previously noticed [18]. We consider these rate factors to be outliers. For these sites, we have observed that likelihood changes very little over a wide range of the α values. An empirical method is used to reduce the values of α_{ ML }outliers, guided by the α_{ AB }values. a Z-score of the ratio of α_{ ML }to α_{ AB }is calculated for each site except invariant sites:
Amino acid frequency vector π optimization
Two methods are implemented to estimate the equilibrium frequency vector π, one derived directly from the given alignment (Alignment-Based π or π_{ AB }) and the other estimated by Maximum Likelihood (π_{ ML }). The likelihood for the entire alignment is a function of π with 19 variables. A continuous minimization method by simulated annealing [40] is used to optimize π, with the objective function being the logarithm likelihood of the alignment. The simulated annealing is computationally intensive and is the major reason for the long CPU time given in Table 2.
Distance matrix calculation and tree inference
A Maximum Likelihood approach is used to estimate the evolutionary distances among sequences, either considering rate variation across sites or not. The logarithm likelihood for replacing one protein sequence (A) with another protein sequence (B) after an evolutionary distance d can be written as:
An estimate of the evolutionary distance between two sequences is obtained by maximizing the likelihood function of equation (15):
Equation (16) can be solved by the bisection root-finding method [40].
After the distance matrix is calculated, the "Weighbor" method, i.e. weighted neighbor joining, is used to infer an evolutionary tree [10].
Ancestral sequence reconstruction
Two methods are implemented to reconstruct ancestral sequences. One is a marginal reconstruction method [4], and the other is a joint reconstruction method [5]. Below are their brief descriptions.
The marginal reconstruction method [4]
We calculate P(A_{ r }|{A_{ l }}T), which is the conditional probability of amino acid A_{ r }at the root, given leaf node amino acid set {A_{ l }} and a tree T. Since time reversibility is assumed, any internal node can serve as a root. Using Bayes' theorem, we have:
Here, P(A_{ r }) is used here instead of P(A_{ r }|T) because the frequency of the root amino acid A_{ r }, i.e. π_{ r }, does not depend on tree T. P({A_{ l }}|A_{ r }T) is the conditional probability of the known amino acids at the leaf nodes, given T and A_{ r }. P({A_{ l }}|T) does not depend on A_{ r }, so it is calculated as a normalization constant for P(A_{ r }|{A_{ l }},T) terms over all 20 possible values of A_{ r }to make the sum equal to 1.
For Figure 10, P({A_{ l }}|A_{ r }T) can be expanded as:
If rate factors are used in the reconstruction of the root sequence, we have:
Here, α_{ i }could be either α_{ AB }or α_{ ML }at site i. P(A_{ C },A_{ D },A_{ E },A_{ F }| A_{ A },T)_{ i }is the conditional probability P(A_{ C },A_{ D },A_{ E },A_{ F }| A_{ A },T) at site i.
The joint reconstruction method [5]
The objective of a joint reconstruction method is to find the combination of amino acids for an internal node set {A_{ i }} that maximize the conditional probability of this amino acid combination, given the leaf node amino acid set {A_{ l }} and a tree T, P({A_{ i }}|{A_{ l }},T). Using the Bayes' theorem, we have:
Because P({A_{ l }}|T) is the same for all amino acid combination at internal node set {A_{ i }} this problem becomes finding the maximum of P({A_{ l }}|{A_{ i }},T) *P({A_{ i }}).
The details of a fast algorithm to solve equation (20) can be found in Pupko et al. [5]. We also incorporated site-specific rate factors in this algorithm, in a similar way as equation (19)
Gaps
Due to difficulties with the probabilistic models of gaps, a simplified empirical approach is used to alleviate the problem. We assume that gaps are "supersede" letters. Gaps are considered for each site independently. If a leaf node has a gap instead of an amino acid at a site, this node will be deleted from the tree for this site. After dealing with leaves, we check all internal nodes for children. If an internal node has no children or only one child due to the leaf removal because of gaps, it will be removed from the tree and a gap will be assumed as its reconstructed state.
Simulations of evolutionary process
Two methods of simulating amino acid substitution process were used to test the reliability of reconstruction, rate factors and evolutionary distance estimation. The first simulation method was based on a homogeneous time reversible Markov model. The parameters from Whelan and Goldman [39] were chosen for our model, including the equilibrium frequency vector π and the S matrix. Given the length of a branch from a parent node to one of its child nodes and the amino acid for the parent node, we simulated the substitution process to generate an amino acid for the child node based on the transition probabilities that were calculated using equation (6). For the arbitrarily selected tree shown in Figure 2, we first generated a random sequence of 100 amino acids as the root sequence based on the amino acid frequencies from Whelan and Goldman [39]. We then simulated the random substitution process to obtain all leaf node sequences. This simulation was repeated 100 times. The resulting 100 alignments were used to test the reliability of the reconstruction result. In this simulation, each site evolved independently according to the same tree topology and branch lengths, thus there was no rate heterogeneity across sites.
The second simulation method, based on a Z-score model, introduced rate variation across sites by using structural and functional information for a specific protein family [21]. We selected three protein families for the Z-score simulations under structural and functional constraints: pdz domain (Protein DataBank (PDB) ID: 1g9o) [41], trypsin (PDB ID: 1sgt) [42] and carboxypeptidase A (PDB ID: 2ctb) [43]. Given a rooted tree, the native sequence with known structure was used as the root sequence. Simulations were made along the tree to generate sequences at any internal node or leaf node. If the evolutionary distance from a parent node to a child node was d, the child sequence was obtained after l*d accepted substitutions starting from the parent sequence, where l is protein sequence length. Simulations of the substitution process were repeated 100 times. For each site, the number of accepted substitutions was recorded and averaged over 100 simulations. Rate factors (observed α), representing site mutability, were calculated from these average substitution numbers, such that the average of rate factors is 1 (equation (10)). 100 simulated alignments were used to test the rate factor estimators (α_{ AB }and α_{ ML }), distance calculation methods and ancestral sequence reconstruction.
Homology detection
Testing dataset
38 OB (Oligonucleotide/oligosaccharide binding)-fold [34] proteins with known structures were selected for homology detection test. OB-fold has a 5-stranded β-barrel structure. In the SCOP (Structure Classification of Proteins) database (version 1.55) [44], there are 7 OB-fold superfamilies. The superfamily of nucleic acid binding proteins is the most populated. Diversity of many OB-fold homologs extends beyond detection by automatic PSI-BLAST searches. Multiple sequence alignments of native sequences were obtained from PSI-BLAST searches starting from the 38 OB-fold sequences with known structures. We also selected 10 alignments (adenylyl kinase, gef, globin, pdz, ph, ptb, ras, sh2, sh3 and subtilase) from the Pfam database (version 7.3) [29] for homology detection test.
Four different methods
For each alignment with N sequences, ancestral sequences for the N-1 internal nodes were reconstructed. The idea is to test whether adding more sequences to a native alignment can help homology detection. Four types of combined alignments were generated, adding different sets of N-1 sequences to the native alignment. In the first case, the added sequence at each internal node consisted of amino acids with the largest probability at each position. In the second case, the added sequences were made up of amino acids with the second largest probability. In the third case, we shuffled the native alignment at each position while keeping the gap pattern as in the native alignment. After shuffling, we added N-1 sequences resulted from the shuffling to the native alignment. In the fourth case, N-1 random sequences were generated with the overall amino acid frequencies of the native alignment. These four methods are named "BEST", "SECOND BEST", "SHUFFLE" and "RANDOM", respectively.
Prediction of functional sites
Our objective is to find sites that are well conserved within each sub-tree, but show high variability between different sub-trees. These sites are likely to contribute to functional specificity [26, 45, 46].
Sequence datasets
Multiple sequence alignments of ten protein families were chosen from the Pfam database (version 7.3) [29]. These families are: adenylyl kinase (adkinase) (representing structure PDB ID: 1aky; its ligand or substrate: AP5) [47], guanine nucleotide exchange factor (gef) (1bkd; H-Ras) [48], globin (1a6g; HEM) [49], pdz domain (1be9; C-terminal peptide of protein CRIPT) [50], ph domain (1mai; I3P) [51], ptb domain (1shc; PTR) [52], ras (821p; GTN) [53], sh2 domain (1a09; ACE) [54], sh3 domain (1nlo; ACE) [55] and subtilase (1av7; SBL) [56]. Most of these alignments contain many sequences. We pruned and clustered the sequences in each alignment according to the length and diversity. Representative sequences were kept and used for tree inference and ancestral sequence reconstruction. This procedure was done in three steps: 1) removing fragments, 2) single-linkage clustering and 3) complete-linkage clustering, as described below.
1. For each family, there is a template sequence with known structure. The sequences, which cover less than 75% of the non-gapped positions in the template sequence with amino acids, were considered to be fragments and discarded.
2. A sequence identity matrix was calculated for the remaining sequences. A single linkage clustering was done to form sequence groups at sequence identity threshold 0.8. For each group, we chose the longest sequence as a representative, discarding other members. This step reduced redundancy in the dataset.
3. An average sequence identity was calculated for the remaining sequences. We used this average identity as a threshold for complete linkage clustering to form new sequence groups. Four groups with the largest sequence numbers were chosen to form our new alignment. Any group with the same number of sequences as the fourth group was also included in the new alignment. The purpose of this step is to keep the major sequence subgroups of a family while leaving out highly divergent sequences that might be deleterious for tree inference.
Rooting
The "Weighbor" method gives an unrooted tree. For our purpose of predicting functional sites, we need to find a point on the tree that serves as the root. We used a least-squares modification of the midpoint rooting procedure to define the root [57].
Tree partitioning
Calculating specificity score for each site
We use {L_{ K }} to represent the set of cutting nodes for layer L_{ K }, K = 0,1,5. {L_{ 0 }} is the root and L_{1} is the closest layer to the root, etc.
A dissimilarity score between any neighboring cutting node pair is calculated. The definition of a neighboring cutting node pair (i, j) (Figure 11) is:
1.i ∈ {L_{ K }}
2.j ∈ {L_{K+1}}
3. Node i is an ancestor of node j (all points on the path from j to root node are ancestors of node j), so that the distance between i and j is exactly d_{ r }/5. Each cutting node has only one ancestral cutting node neighbor.
The dissimilarity score for cutting node j and its ancestral cutting node neighbor i, i.e. anc(j), at site m is defined as:
The specificity score is defined as:
Comparison with other methods
We compared our method with three other methods for prediction of functional sites. The first method (Simple Conservation or SC) is based on sequence conservation. Highly conserved sites are considered to be functional. For each family, we sorted the sites by positional conservation [25] and chose the 10 top-ranking sites as the predictions. There might be ties for sites. For example, if there were 5 sites tied at the tenth conservation value and only one of them was within 5Å from the ligand(s), then its contribution to the total number of "correct predictions" was 1/5. The second method is the evolutionary trace (ET) method [26], which partitions a sequence identity dendrogram into sub-trees at varying sequence identity thresholds. Sites that are invariant within each individual sub-tree are picked as functional sites. A higher identity threshold gives rise to more sub-trees and, since conserved sites are more frequent in the sub-trees with smaller sizes, lead to more predicted sites. ET analysis was performed from a low identity threshold to higher thresholds until the number of predicted sites was 10 or just above 10 (in the cases of ties). Ties were resolved similarly to the simple conservation method. The third method (conservation difference or CD) is based on the conservation differences between a native alignment and an alignment derived from the Z-score sequence design [21]. The basic idea was to differentiate sites conserved due to structural stability and sites conserved due to function. Since the pairwise potential in the Z-score design tends to weaken the conservation caused by function, functionally conserved sites tend to have a large conservation difference between the native alignment and the alignment of designed sequences. We chose 10 top ranking sites sorted by conservation difference as predictions by CD.
Notes
Declarations
Acknowledgements
We thank Lisa Kinch, James Wrabl and Hua Cheng for their useful comments. This work was supported by the NIH grant GM67165 to NVG.
Authors’ Affiliations
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