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Generalizations of Markov model to characterize biological sequences
BMC Bioinformatics volume 6, Article number: 219 (2005)
Abstract
Background
The currently used k^{th}order Markov models estimate the probability of generating a single nucleotide conditional upon the immediately preceding (gap = 0) k units. However, this neither takes into account the joint dependency of multiple neighboring nucleotides, nor does it consider the long range dependency with gap>0.
Result
We describe a configurable tool to explore generalizations of the standard Markov model. We evaluated whether the sequence classification accuracy can be improved by using an alternative set of model parameters. The evaluation was done on four classes of biological sequences – CpGpoor promoters, all promoters, exons and nucleosome positioning sequences. Using di and trinucleotide as the model unit significantly improved the sequence classification accuracy relative to the standard single nucleotide model. In the case of nucleosome positioning sequences, optimal accuracy was achieved at a gap length of 4. Furthermore in the plot of classification accuracy versus the gap, a periodicity of 10–11 bps was observed which might indicate structural preferences in the nucleosome positioning sequence. The tool is implemented in Java and is available for download at ftp://ftp.pcbi.upenn.edu/GMM/.
Conclusion
Markov modeling is an important component of many sequence analysis tools. We have extended the standard Markov model to incorporate joint and long range dependencies between the sequence elements. The proposed generalizations of the Markov model are likely to improve the overall accuracy of sequence analysis tools.
Background
Biological complexity has evolved through a combination and interactions between simpler units. By looking at these units in a context dependent way, we can better understand the biological complexity. For example, Wang and Feng explored the amino acid propensity pattern in a neighbordependent way and found that the patterns were not always predictable from the single amino acid patterns [1]. Application of these diamino acid propensity patterns into a traditional NeedlemanWunsch [2] algorithm significantly improved protein sequence alignment [3]. Similarly one can better predict the transcription factor binding sites by considering the interdependence between nucleotides [4, 5].
Markov model (MM) is a statistical technique to model sequences such that the probability of a sequence element is based on a limited context preceding the element [6, 7]. In other words, MM is a way to factorize the probability of observing the sequence in terms of contextdependent probabilities of the sequence elements. It has been effectively used in many DNA sequence recognition problems such as promoter and gene prediction [8]. The standard k^{th} order MM assumes that a sequence element probability depends on k previous bases, immediately preceding the current base. Alternatively, the standard Markov Model generates a single base (model unit size = 1) according to a probability distribution depending on the k bases immediately preceding the generated base (gap = 0).
The biological rationale behind selecting these parameters is not clear and alternatives should be explored. Longer range dependencies and joint dependency of neighboring bases have been observed in protein and DNA sequences. For instance, CG dinucleotide is what characterizes CpG islands [1, 9]. In bacterial promoters, a regular positioning of TA and TG stacks is prevalent with the best fit period 5.6 bp [10]. Stacking between neighboring bases is an important source of enthalpy change on helix formation [11]. In the study by Ozoline et al. the period of 5.6 bps for TA and TG can be interpreted as half of the helical repeat period with a contribution from a sequencedependent helical writhe of the promoter DNA [10]. A repetition of certain dinucleotide at 10–11 bp has been discovered in numerous genomes, supporting the DNA wrapping around the nucleosomes [12]. A model with unit size of 2 might be more appropriate to characterize the joint dependency of CG dinucleotide. Furthermore, longer range dependencies (gap > 0) should be explored to model the periodicity of helix pattern. These alternative hypotheses regarding the positional and joint dependence within sequences can be computationally evaluated by extending the Markov Models.
There have been attempts to generalize Markov models. The Mixture Transition Distribution Model conditions the current state on a combination of previous states at varying distances [13]. In the spatial model, the current nucleotide depends on both the left and the right nucleotides [14]. For a detailed review of other generalizations and their limitations see [15]. We have developed a configurable tool to allow for generalizations of Markov model (GMM), as described in the implementation section.
We have evaluated a few instances of our GMM for their ability to classify four classes of sequences – CpGpoor promoters, all promoters, exons and nucleosome positioning sequences against appropriate background sequences. We compared two special cases of our model, the third order dinucleotide (model unit size = 2) and 2^{nd} order trinucleotide (model unit size = 3) GMM against the traditional 6^{th} order single nucleotide Markov model. Our results based on 10fold cross validation show that the dinucleotide and the trinucleotide based models are significantly better than the single nucleotide based models. Furthermore, in the case of nucleosome positioning sequences, a gap length of 4 achieves the optimal classification accuracy. By allowing us to explore the dependence structure, the GMM tool will not only improve the classification accuracy of a sequence class, but will also provide insights into the structural properties of the sequences.
Implementation
We define the bases whose probability we wish to compute as the posterior bases or simply the posterior and the bases on which this probability is conditioned upon, as the prior. We use six parameters to specify a Markov model (as shown in Figure 1). To capture the joint dependency of neighboring nucleotides, our model allows multiple nucleotides as the model unit. However we allow different model unit sizes for the prior and the posterior, denoted as L_{ 1 }and L_{ 2 }respectively. The gap between the posterior and prior is denoted by G. The prior is composed of a few individual model units. The number of such units is called order. The maximum order is denoted by O. We also allow these individual prior units to be at an arbitrary spacing from each other. This spacing between the prior units is denoted by g_{ 1 }. Lastly, within the bases comprising the posterior we allow arbitrary spacing between the bases denoted as g_{ 2 }. For instance a spacing of length 2 within a posterior model unit of size 2 in an amino acid sequence captures the joint dependency for the first and the fourth amino acid residue, which is likely to form a hydrogen bond – vital for the protein helix structure [16]. To evaluate a model where each trinucleotide depends on the previous 4 bases, one can set L_{ 1 }= 4, 0 = 1, L_{ 2 }= 3, g_{ 1 }= g_{ 2 }= G = 0. To use the four bases after ignoring the immediately preceding 3 bases, one can set G = 3.
The prior order O only specifies the maximum order. Our program uses the idea of variable length Markov model [17] such that the highest order for which sufficient data is available, is utilized [18, 19]. Apart from the 6 parameters mentioned above, the other generic configurable parameters include: type of biological sequence, either protein ('P') or DNA ('N'); threshold for minimal count of prior for kmer elimination; pseudo count for a kmer absent in the training set and the phase the user wants to score. For further information on the parameters, please refer to the software package readme file. Given a particular configuration, our implementation of the GMM is very similar to that of GLIMMER package, with a few exceptions.
Training
In order to achieve statistical robustness, we only consider the kmers above a (configurable) frequency threshold in the positive sequences. This frequency must ensure that the estimated conditional probabilities are acceptably close to true probabilities. A frequency threshold of 400 was estimated in [19] that provided a 95% confidence that the estimated probabilities were within 0.05 from the true ones. We tried varying this threshold from 50 to 500 and it did not make a significant difference in performance (also observed in [19]) and attains the maximum at 300. Hence we chose this as the default threshold. For nucleosome sequences we chose 50 as the frequency threshold due to smaller data set.
We slide the window one base at a time along the training sequence. The window size is determined by the user defined parameters; window size = L_{ 1 }× O + g_{ 1 }× (O1) + G + L_{ 2 }+ g_{ 2 }× (L_{ 2 }1). For each window, we extract the words corresponding to the prior and the posterior. For example, for L_{ 1 }= 1, O = 6, L_{ 2 }= 2, g_{ 1 }= 0, G = 1, g_{ 2 }= 1, we have a window with length 10, say ACTGATGCAG. The dinucleotide CG represents the posterior. We increment the counts of kmers ACTGATCG (6^{th} order), CTGATCG (5^{th} order), ..., and CG (0^{th} order) by one. We thus have 7 submodels, one for each order.
Once the training sequences are processed, we convert the raw counts into transition probabilities. For the 0^{th} order, the probability is the composition of the L_{ 2 }mers. For higher order, say, 4^{th} order TGATCG, we compute the sum of frequencies of all the hexamers of the form TGAT**. If the sum is bigger than the user specified threshold, we calculate the probability by dividing the count of TGATCG by the sum. Otherwise, the program automatically uses the (k1)mer, and so on to order 0, where the base composition is used. The same process is repeated for the background training sequences and we thus obtain a negative model. We then convert the probability for each kmer into logodds score.
Testing
The program first reads in the model – the kmer logodds – along with the configuration file. Scoring proceeds in a sliding window fashion where each window is the minimal sequence containing a posterior and the prior as described above. To score a window, we first consider the highest order. Using the example above, to score ACTGATG CA G (the underscored bases correspond to gaps in the model), we first look for 6^{th} order dependence, ie., ACTGATCG in the 8mer table. If the string exists, we use the score. Otherwise, we look for the string corresponding to the 5^{th} order (CTGATCG), and so on, until the 0^{th} order, ie., the dinucleotide composition. The sequence score is obtained by adding all window scores. We score the sequence using two models corresponding to the positive and the negative sequences.
For posterior length L_{ 2 }, the overall sequence score can be interpreted as the sum of the scores of L_{ 2 }independent parses of the sequence in different phases. In each parse or phase, any given base is generated exactly once. We will illustrate this with an example. Let L_{ 2 }= 3, and g_{ 2 }= 1. Consider a test sequence S = s_{ 1 }s_{ 2 }...s_{ n }. The posterior P_{ i }starting at i^{th} position is s_{ i }s_{i+2}s_{i+4}. Each P_{ i }is in a specific phase φ_{k}, 1 ≤ κ ≤ L_{ 2 }. Under φ_{1} we consider P_{ 1 },P_{ 2 },P_{ 7 },P_{ 8 },P_{ 13 },P_{ 14 }, .... We jump from P_{ 2 } to P_{ 7 }, since all bases from s_{ 1 }to s_{ 6 }are covered by P_{ 1 }and P_{ 2 }. Similarly under φ_{2} we consider P_{ 3 },P_{ 4 },P_{ 9 },P_{ 10 },P_{ 15 },P_{ 16 }, .... Hence the phases for P_{ i }, i = 1,2,3..... are 1,1,2,2,3,3,1,1,2,2,3,3.... Note that each base position is covered exactly once in any of the three phases. If one has a prior knowledge of sequence phase (eg. inphase exons) and does not wish to use the sum of all phases as a sequence score, one can specify a particular phase to be used. The model will use only the posteriors in that specific phase for training and scoring.
Results
The human promoter sequences
We extracted the ± 5 kb region around the 12,333 Transcriptional Start Site (TSS) in the DBTSS database [20]. These start sites are identified using oligocapping approach. We have implemented a slidingwindow based program to identify CpGislands using the original definition of CpGislands [21]. We have also implemented a Hidden Markov Model (HMM) approach for CpG island identification [7]. We call a 10 kb promoter region CpGpoor if it does not contain a 200 bp length CpGisland by either of the two methods. This resulted in 1,466 CpGpoor promoters from a total of 12,333 promoter sequences. We then randomly selected 5,000 10 kb sequences from the whole human genome after masking the DBTSS promoter regions. The 5,000 background sequences and the 1,466 CpGpoor promoters were used to evaluate the various models. The same background dataset was also used for the classification of the entire set of 12,333 promoter sequences.
The human exon dataset
The human exon locations were downloaded from UCSC genome browser, human genome version hg16. We extracted the exon sequences based on start and end locations. We thus obtained 219,624 exons. To compile a background sequence set, we randomly selected the same length sequences from the background for each exon.
The nucleosome positioning sequences
The nucleosome positioning sequences were downloaded from the Nucleosome Positioning Region Database (NPRD) [22, 31]. The generation of background sequences was done similarly to the exon dataset.
Model evaluation
We used 10fold crossvalidations to train and test the models. The positive and the background sequences were randomly partitioned into 10 equal parts. Each part was tested after training on the other 9 parts. Once the models were trained, we scored the training set using the models and obtained a cutoff based on the specificitysensitivity curve. We chose a score cutoff that resulted in the best correlation coefficient (CC) value for the training set. We then scored the (independent) test set and applied this cutoff to obtain the CC value. The mean and standard deviation over the 10 CC values was calculated. The Sensitivity (S_{e}), Specificity (S_{p}) and Correlation coefficient (CC) values were defined as following:
TP: True positive, FP: False positive, TN: True negative, FN: False negative.
We have provided scripts to evaluate a specified configuration based on 10fold cross validation. This involves scripts for splitting the input sequence into 10 equal parts and code for calculating the sensitivity, specificity and correlation coefficient.
To assess the significance of the performance improvement using a model M compared to base model M* (standard MM), we used Wilcoxon paired rank sum test. All sequences (positive and background) were scored using M to obtain score list S and using M* to obtain score list S*. Both S and S* were normalized separately to mean 0 and standard deviation 1. These paired normalized scores for positive sequences (each sequence has 2 scores corresponding to the 2 models) were used to test whether the scores in S* are greater than the corresponding scores in S using Wilcoxon test.
We have applied specific configurations of the tool to a few biological sequence classification problems as an illustration. Specifically to evaluate the impact of varying model unit size we used the following three settings:

(1)
6^{th} order single nucleotide model: L_{ 1 }= L_{ 2 }= 1, O = 6, g_{ 1 }= 0, G = 0, g_{ 2 }= 0,

(2)
3^{rd} order dinucleotide model: L_{ 1 }= L_{ 2 }= 2, O = 3, g_{ 1 }= 0, G = 0, g_{ 2 }= 0,

(3)
2^{th} order trinucleotide model: L_{ 1 }= L_{ 2 }= 3, O = 2, g_{ 1 }= 0, G = 0, g_{ 2 }= 0.
The 6^{th} order singlenucleotide Markov Model is common in many sequence analysis tools currently used. Notice that the total number of prior bases is six for each of these three models. We tested the classification accuracy for three sequence classes using the above three configurations. The results for CpGpoor promotes, all promoters and all exon classifications are showed in Table 1, and discussed below.
Classification of CpGpoor promoters
The di and tri nucleotide models improve upon single nucleotide model (pvalue < 0.001). The traditional (singlenucleotide) 6^{th} order Markov model yielded a correlation coefficient value (CC) of 0.24. When we use the tri nucleotide model, the CC value was improved by 39% to 0.34. The specificitysensitivity graph (Figure 2) further shows the sensitivityspecificity tradeoff. For instance, at a reference sensitivity value of 0.5, the specificity achieved by the trinucleotide based model is 0.52, as compared to 0.36 for the singlenucleotide model.
Classification of all promoters
We next applied the models to classify the entire set of 12,333 promoter sequences. The trinucleotide model shows an improvement in the classification accuracy (0.58 versus 0.54, pvalue < 0.001) relative to the single nucleotide model. The entire set of promoters is dominated by CpG associated promoters which by virtue of being GCrich and containing CpG islands have a strongly distinguishable characteristics against the background sequences. Consequently the relative gains of using larger model units are marginal.
Classification of exons
We extracted 219,624 annotated exons from the hg16. We randomly selected the 219,624 sequences with the same length as the exons from background sequences. The average correlation coefficient for classification accuracy for single, di, and trinucleotide models are 0.63, 0.645 and 0.66 respectively. This modest improvement is however statistically significant.
Classification of nucleosome positioning sequences
A periodical distribution pattern of transcription factor sites was observed in promoter region that suggested a correlation between the positioning of nucleosomes and transcription factor binding sites [23]. To investigate the nucleosome sequence periodicity, we compared classification accuracy at different gap length (parameter G) between prior and posterior. We were able to obtain 112 nucleosome sequences and performed their classification based on the first order trinucleotide model (L_{ 1 }= 3, O = 1, g_{ 1 }= 0, L_{ 2 }= 3, g_{ 2 }= 0) at varying values of G. We achieve the best classification accuracies at G = 4, 15 and 25, and worst classification accuracies at G = 7 and 18 (Figure 3). The distances between consecutive peaks and valleys are around 10–11 bps, which is close to DNA helix turn of 10.5 bps (for most common BDNA, 11 bps for ADNA, 12 bps for ZDNA).
Run time
We compared the run time for the three models on training and testing of the CpGpoor promoter classification against the background. The benchmark was based on 64 Mb sequences with parameters described in the method section. The java program was tested on a 2.6 GHz Pentium III dual processors with 16GB of RAM running linux. The training time for singlenucleotide based model was 55.8 minutes. This reduced to 23.8 and 18.9 minutes for the di and trinucleotide based models respectively. The time needed for testing reduces less significantly by 30%40%, from 22.9 minutes for single to 15.4 and 14.0 minutes for di and tri nucleotide models respectively. The run time reductions are mainly due to fewer orders the model needs to go though for di and tri nucleotide models.
Discussion
Markov chains are commonly used to model biological sequences. However the specific model unit size and the dependence structure among the sequence elements have not been explored. Specifically the model unit is fixed as a single nucleotide or amino acid and its dependence on k elements immediately preceding the current element is incorporated in the model. We have argued that it might be better to consider different model unit size and dependence structures. Furthermore, it has been reported that the optimal choice of model type and the model order is species specific [18]. Hence, it is important to implement the modeling tool in a configurable fashion.
Promoter prediction
Despite numerous efforts in promoter prediction, the subclass of promoters not associated with CpG islands or CpGpoor promoters are notoriously difficult to characterize and predict. This remains the main bottleneck in overall promoter prediction accuracy and an accurate analysis of transcriptional regulation [24–26]. One component of promoter prediction is a better characterization of overall DNA structural feature in the vicinity of the promoters. Consistent with other studies that by considering the neighboring dependency of amino acids can improve the protein sequence alignment [3], here we show that by using the longer Markov unit to capture the joint dependency of neighboring nucleotides, we can substantially improve the CpGpoor promoter classification. Although we are not proposing an improved promoter prediction tool here, our result does suggests an alternative modeling of the long range DNA characteristics which is likely to improve the overall promoter prediction.
Nucleosome positioning (NP) sequence prediction
The nucleosome is the basic unit of chromatin. Regulation of eukaryotic gene transcription is closely linked with the changes in nucleosome structure of the chromatin [22]. A nucleosome at the promoter region is capable of inhibiting the transcription initiation, whereas its displacement is capable of surmounting the repressive effect [27]. The preference of various sequences to allow for NP is not clear. An interesting aspect of our application of GMM to NP sequences is the observation that a gap length of 4 better captures the local dependence in these sequences. This, along with the periodicity of 10–11 bps in the plot of classification accuracy against the gap length might indicate a structural requirement in proteinDNA interaction in the NP.
Generalizations of MM
Two main challenges in generalizing Markov models are (i) ensuring that the score of a sequence given the model can be appropriately factorized in terms of individual model unit scores (each base is included in exactly one model unit, modulo the edge effects), and (ii) accurate parameter estimation. We have shown that the sequence score can be interpreted as sum of scores using L_{ 2 }independent parses of the sequence, where L_{ 2 }is the number of posterior bases. Score of the sequence for each phase can indeed be factorized in terms of scores of disjoint posteriors. However with respect to accurate parameter estimation we have adopted a simple strategy analogous to that for standard MM and the parameter estimation methods developed in [15] may provide more accurate models.
We have used the sum of scores in different phases as the overall sequence score. Using the maximum score among all phases presents another alternative, which might be appropriate for coding exons where the codon impose a phase. When we do not have such a priori knowledge, then using maximum among phase scores may be inappropriate. Also it can be computationally prohibitive since one will need to build separate model of each phase and when scoring a sequence, try all models for all phase structure of the sequence. Thus the computational time for scoring a sequence is L_{2} *L_{2} – fold greater than the phaseless scoring. In our current implementation, for the cases where there is a prior knowledge of phase, users can specify a phase parameter, such that the model is built for a specific phase and also applied to the same phase.
Conclusion
We have developed a configurable tool to explore generalizations of Markov models incorporating joint and long range dependencies of the sequence elements. As an illustration, we have shown that by using longer kmer as Markov model units and specific gap lengths, one can improve the classification accuracy for a variety of biologically important sequence classes. Various tools to predict biological sequences like promoters and genes exploit multiple sequence based characteristics. The long range DNA characteristics are commonly captured using Markov models, eg Genscan [28] and HMMgene [29]. An improvement in this aspect of the prediction has direct implications on overall prediction accuracy of these tools. A complete theoretical development of generalizations of Markov models will require further research. The proposed software provides a means to explore dependency structures for a novel sequence class.
Availability and requirements
The software will be freely available for download ftp://ftp.pcbi.upenn.edu/GMM/. The program requires java version 1.4.2 or above to run, and it is platform independent. Please refer to software package for detailed instruction on how to run the programs.
Abbreviations
 MM:

– Markov model
 GMM:

– Generalizations of markov model
 TSS:

– Transcription start site
 DBTSS:

– Data base of transcription start sites
 NP:

– Nucleosome positioning
 NPRD:

– Nucleosome positioning region database
 CC:

– Correlation coefficient
References
 1.
Wang J, Feng JA: Exploring the sequence patterns in the alphahelices of proteins. Protein Eng 2003, 16: 799–807. 10.1093/protein/gzg101
 2.
Needleman SB, Wunsch CD: A general method applicable to the search for similarities in the amino acid sequence of two proteins. J Mol Biol 1970, 48: 443–453. 10.1016/00222836(70)900574
 3.
Wang J, Feng JA: NdPASA: a novel pairwise protein sequence alignment algorithm that incorporates neighbordependent amino acid propensities. Proteins 2005, 58: 628–637. 10.1002/prot.20359
 4.
Bulyk ML, Johnson PL, Church GM: Nucleotides of transcription factor binding sites exert interdependent effects on the binding affinities of transcription factors. Nucleic Acids Res 2002, 30: 1255–1261. 10.1093/nar/30.5.1255
 5.
Zhou Q, Liu JS: Modeling withinmotif dependence for transcription factor binding site predictions. Bioinformatics 2004, 20: 909–916. 10.1093/bioinformatics/bth006
 6.
Davis MHA: Markov Models & Optimization. In Monographs on statistics and applied probability. Volume 49. , CHAPMAN & HALL; 1993.
 7.
Durbin R, Eddy S, Krogh A, Mitchison G: Biological Sequence Analysis. 1998.
 8.
Ohler U, Niemann H: Identification and analysis of eukaryotic promoters: recent computational approaches. Trends Genet 2001, 17: 56–60. 10.1016/S01689525(00)021740
 9.
GardinerGarden M, Frommer M: CpG islands in vertebrate genomes. J Mol Biol 1987, 196: 261–282. 10.1016/00222836(87)906899
 10.
Ozoline ON, Deev AA, Trifonov EN: DNA bendabilitya novel feature in E. coli promoter recognition. J Biomol Struct Dyn 1999, 16: 825–831.
 11.
Dimitrov RA, Zuker M: Prediction of hybridization and melting for doublestranded nucleic acids. Biophys J 2004, 87: 215–226. 10.1529/biophysj.103.020743
 12.
Schieg P, Herzel H: Periodicities of 10–11bp as indicators of the supercoiled state of genomic DNA. J Mol Biol 2004, 343: 891–901. 10.1016/j.jmb.2004.08.068
 13.
Raftery AE: A model for high order Markov chains. J Roy Statst Soc Ser 1985, B47: 528–539.
 14.
Berchtold A: Estimation in the mixture transition distribution model. J TIme Ser Anal 2001, 22: 379–397. 10.1111/14679892.00231
 15.
Berchtold A, Raftery AE: The mixture transition distribution model for highorder Markov chains and nonGaussian time series. Statistical Science 2002, 17: 328–356. 10.1214/ss/1042727943
 16.
Penel S, Morrison RG, MortishireSmith RJ, Doig AJ: Periodicity in alphahelix lengths and Ccapping preferences. J Mol Biol 1999, 293: 1211–1219. 10.1006/jmbi.1999.3206
 17.
Buhlmann P, Wyner AJ: Variable length markov chains. The Annals of Statistics 1999, 27: 480–513. 10.1214/aos/1018031204
 18.
Azad RK, Borodovsky M: Effects of choice of DNA sequence model structure on gene identification accuracy. Bioinformatics 2004, 20: 993–1005. 10.1093/bioinformatics/bth028
 19.
Salzberg SL, Delcher AL, Kasif S, White O: Microbial gene identification using interpolated Markov models. Nucleic Acids Res 1998, 26: 544–548. 10.1093/nar/26.2.544
 20.
Suzuki Y, Yamashita R, Nakai K, Sugano S: DBTSS: DataBase of human Transcriptional Start Sites and fulllength cDNAs. Nucleic Acids Res 2002, 30: 328–331. 10.1093/nar/30.1.328
 21.
Antequera F, Bird A: Number of CpG islands and genes in human and mouse. Proc Natl Acad Sci U S A 1993, 90: 11995–11999.
 22.
Levitsky VG, Katokhin AV, Podkolodnaya OA, Furman DP, Kolchanov NA: NPRD: Nucleosome Positioning Region Database. Nucleic Acids Res 2005, 33 (Database Issue): D67–70.
 23.
Ioshikhes I, Trifonov EN, Zhang MQ: Periodical distribution of transcription factor sites in promoter regions and connection with chromatin structure. Proc Natl Acad Sci U S A 1999, 96: 2891–2895. 10.1073/pnas.96.6.2891
 24.
Davuluri RV, Grosse I, Zhang MQ: Computational identification of promoters and first exons in the human genome. Nat Genet 2001, 29: 412–417. 10.1038/ng780
 25.
Hannenhalli S, Levy S: Promoter prediction in the human genome. Bioinformatics 2001, 17 Suppl 1: S90–6.
 26.
Bajic VB, Tan SL, Suzuki Y, Sugano S: Promoter prediction analysis on the whole human genome. Nat Biotechnol 2004, 22: 1467–1473. 10.1038/nbt1032
 27.
Li G, Chandler SP, Wolffe AP, Hall TC: Architectural specificity in chromatin structure at the TATA box in vivo: nucleosome displacement upon betaphaseolin gene activation. Proc Natl Acad Sci U S A 1998, 95: 4772–4777. 10.1073/pnas.95.8.4772
 28.
Burge C, Karlin S: Prediction of complete gene structures in human genomic DNA. J Mol Biol 1997, 268: 78–94. 10.1006/jmbi.1997.0951
 29.
Krogh A: Two methods for improving performance of an HMM and their application for gene finding. Proc Int Conf Intell Syst Mol Biol 1997, 5: 179–186.
Acknowledgements
The authors would like to thank Joan Gu in the lab for compiling part of the dataset. We thank Dr. Yutaka Suzuki for kindly providing us the fulllength promoter sequences and Bill Majoros for assistance on the GLIMMER package. Special thanks to reviewers for thoughtful comments.
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JW and SH were involved in the developing the idea and writing the manuscript. JW implemented the software.
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Wang, J., Hannenhalli, S. Generalizations of Markov model to characterize biological sequences. BMC Bioinformatics 6, 219 (2005). https://doi.org/10.1186/147121056219
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Keywords
 Classification Accuracy
 Model Unit
 Nucleosome Position
 Promoter Prediction
 Background Sequence