# Statistical potential for assessment and prediction of protein structures

## Abstract

Protein structures in the Protein Data Bank provide a wealth of data about the interactions that determine the native states of proteins. Using the probability theory, we derive an atomic distance-dependent statistical potential from a sample of native structures that does not depend on any adjustable parameters (Discrete Optimized Protein Energy, or DOPE). DOPE is based on an improved reference state that corresponds to noninteracting atoms in a homogeneous sphere with the radius dependent on a sample native structure; it thus accounts for the finite and spherical shape of the native structures. The DOPE potential was extracted from a nonredundant set of 1472 crystallographic structures. We tested DOPE and five other scoring functions by the detection of the native state among six multiple target decoy sets, the correlation between the score and model error, and the identification of the most accurate non-native structure in the decoy set. For all decoy sets, DOPE is the best performing function in terms of all criteria, except for a tie in one criterion for one decoy set. To facilitate its use in various applications, such as model assessment, loop modeling, and fitting into cryo-electron microscopy mass density maps combined with comparative protein structure modeling, DOPE was incorporated into the modeling package MODELLER-8.

**Keywords:**statistical potential, protein structure prediction, comparative or homology modeling, model assessment

The native structure generally has the lowest free energy of all states under the native conditions (Anfinsen 1972, 1973). Therefore, an accurate free energy function would enable the prediction and assessment of protein structures (Dill 1985, 1997; Bryngelson et al. 1995; Dobson et al. 1998; Shakhnovich 2006). In principle, the free energy surface of a protein can be derived by thoroughly sampling the potential energy surface defined by a molecular mechanics force field (Brooks et al. 1988). However, this approach is computationally prohibitive and may be further limited by errors in potential energy functions. Instead of relying on free energy, an alternative approach is to construct a scoring function whose global minimum also corresponds to the native structure from a sample of native structures of different sequences (Tanaka and Scheraga 1976; Miyazawa and Jernigan 1985; Sippl 1990) deposited in the Protein Data Bank (PDB) (Kouranov et al. 2006). Due to its dependence on known protein structures, such a scoring function is often termed a knowledge-based or statistical potential.

The pioneering work of Tanaka and Scheraga (1976) related the frequencies of contact between different residue types, obtained from known native structures, to the free energies of corresponding interactions using the simple relationship between free energy and the equilibrium constant. Their work was followed by that of Miyazawa and Jernigan (1985, 1996, 1999), who developed residue contact statistical potentials using a quasichemical approximation. A new form of a statistical potential dependent on a distance between two residue types was then proposed independently by Sippl (1990, 1993a, b), based on the assumption that the distributions of distances between different residue types in diverse native structures in PDB are Boltzmann-like.

Subsequently, a large number of different statistical potentials were described and tested (Hendlich et al. 1990; Colovos and Yeates 1993; Sippl 1993a; Kocher et al. 1994; Huang et al. 1995; Rooman and Wodak 1995; Jernigan and Bahar 1996; Jones and Thornton 1996; Miyazawa and Jernigan 1996; Moult 1997; Park and Levitt 1996; Park et al. 1997; Reva et al. 1997; Simons et al. 1997; Vajda et al. 1997; Furuichi and Koehl 1998; Melo and Feytmans 1998;Rooman and Gilis 1998; Samudrala and Moult 1998; Betancourt and Thirumalai 1999; Jones 1999b; Rojnuckarin and Subramaniam 1999; Simons et al. 1999; Bastolla et al. 2000; Chiu and Goldstein 2000; Gatchell et al. 2000; Lazaridis and Karplus 2000; Vendruscolo et al. 2000; Lu and Skolnick 2001; Melo et al. 2002; Keasar and Levitt 2003; Zhou and Zhou 2003; Betancourt and Skolnick 2004; Buchete et al. 2004a,b; Wang et al. 2004; Zhang et al. 2004; Chen and Shakhnovich 2005; Fang and Shortle 2005; Qiu and Elber 2005; Summa et al. 2005; Dehouck et al. 2006; Eramian et al. 2006). Statistical potentials can be classified by the following characteristics: (1) protein representation (e.g., centroids of amino acid residues, C_{α}/C_{β} atoms, and all atoms), (2) the restrained spatial feature (e.g., solvent accessibility, contact, distance, torsional angle), and (3) the reference state. Statistical potentials for the all-atom representation are generally more accurate than those for an amino acid residue representation (Samudrala and Moult 1998; Lu and Skolnick 2001; Melo et al. 2002; Zhou and Zhou 2002). The most commonly used statistical potentials depend on atomic distances only.

Statistical potentials are widely used in numerous applications because of their relative simplicity, accuracy, and computational efficiency. These applications include assessment of experimentally determined and computationally predicted protein structures (Sippl 1993b; DeBolt and Skolnick 1996; Gatchell et al. 2000; Melo et al. 2002; John and Sali 2003; Wang et al. 2004; Topf and Sali 2005; Topf et al. 2006), ab initio protein structure prediction (Bowie et al. 1991; Sun 1993; O'Donoghue and Nilges 1997; Chiu and Goldstein 2000; Tobi and Elber 2000; Tobi et al. 2000), fold recognition or threading (Maiorov and Crippen 1992; Sippl and Weitckus 1992; Bryant and Lawrence 1993; Ouzounis et al. 1993; Huang et al. 1995; DeBolt and Skolnick 1996; Jones and Thornton 1996; Reva et al. 1997; Jones 1999a; Kolinski et al. 1999; Miyazawa and Jernigan 1999, 2000; Panchenko et al. 2000; Skolnick et al. 2000), detection of native-like protein conformations (Hendlich et al. 1990; Casari and Sippl 1992; Bauer and Beyer 1994; Samudrala and Moult 1998; Simons et al. 1999; Gatchell et al. 2000; Vendruscolo et al. 2000), and prediction of protein stability (Gilis and Rooman 1996, 1997).

Perhaps the most essential question in the derivation of a statistical potential is how best to formulate and interpret a scoring function derived from a sample of native structures. In general, the derivation of a statistical potential has been motivated by a presumed analogy between a sample of native structures and the canonical ensemble in statistical mechanics. The principal of the corresponding assumptions is that the distributions of different structural features obtained from a sample of native structures obey the Boltzmann distribution of statistical mechanics (Sippl 1990). However, such a sample contains native states of different sequences at different temperatures, not states of the same sequence over a longer period of time at a specific temperature (Thomas and Dill 1996b), as required by the definition of the canonical ensemble to which the Boltzmann distribution applies. Therefore, alternative interpretations of the origin of the Boltzmann-like distribution for structural features in a sample of native structures have also been suggested (Finkelstein et al. 1995). In this other view, the Boltzmann-like distribution is a consequence of evolution that favors structural features for which more sequences have the global free energy minimum.

As a result of the uncertainties in the very formulation of a statistical potential, there are several related problems, including the question of the most appropriate reference state (Skolnick et al. 1997), the additivity of the individual terms in a statistical potential (BenNaim 1997), as well as balancing of a statistical potential with other terms that may be used in a complete scoring function for protein structure prediction (Misura et al. 2006).

Here, we first identify a statistical potential with the negative logarithm of the joint probability density function of a given protein. We then derive an atomic distance-dependent statistical potential from a sample of native structures based entirely on the probability theory, without recourse to statistical mechanics, thus circumventing the assumption of the Boltzmann distribution. Subsequently, we clarify the assumptions and approximations needed to interpret a statistical potential as a potential of mean force. This approach allowed us to treat the problem of the reference state more accurately than has been done previously. In our theory, the reference state is a finite sphere of uniform density and appropriate size, instead of the distribution of interatomic distances in the sample native structures irrespective of their sizes and atom types. In other words, in contrast to the previous approaches, our reference state explicitly depends on the sizes of the native structures from which the statistical potential is derived. This improvement results in an increased accuracy of protein structure assessment, as demonstrated by testing various statistical potentials, including ours, on multiple decoy sets. We term our new statistical potential Discrete Optimized Protein Energy (DOPE).

We begin by deriving DOPE from a sample of the native structures (see Theory). Next, we describe its accuracy compared to five other scoring functions with the aid of six multiple target decoy sets (see Results). We proceed by discussing its relative successes, failures, and applications (see Discussion). A detailed description of the training and decoy sets, the evaluated scoring functions, and the evaluation criteria are provided in Materials and Methods.

## Theory

In this section, we describe the theory of the Discrete Optimized Protein Energy (DOPE). DOPE is an atomic distance-dependent statistical potential calculated from a sample of native protein structures. It is grounded entirely in the probability theory. We first define a statistical potential as the negative logarithm of the joint probability density function (pdf) of the atomic Cartesian coordinates. We then express the joint pdf as a product of pair pdfs. Next, we derive the pair pdf from a distance pdf, extracted from a single sample native structure and a reasonable definition of the reference state. Finally, we show how to combine the pair pdfs from a sample of many native structures of varying size to obtain the joint pdf. We conclude this section by clarifying the assumptions and approximations needed to connect our statistical potential and a potential of mean force.

### Joint pdf for a native structure as a product of pair pdfs

Prediction of the native structure of a protein would be enabled by expressing our knowledge of any kind as a scoring function whose global optimum corresponds to the native structure. One such function is a joint probability density function of the Cartesian coordinates of the protein atoms, given available information *I* about the system, , where *N* is the number of atoms in the protein and are the Cartesian coordinates of atom *i*. For each atom in a given protein, the joint pdf *p* gives the probability density that the atom *i* of the native structure is positioned very close to , given the information *I* we wish to consider in the calculation. In general, information *I* may include the sequence of the protein, a molecular mechanics force field, experimental structural information, a sample of known native structures, and an alignment of the sequence to a related known protein structure. For example, when information *I* reflects only the sequence and the laws of physics under the conditions of the canonical ensemble, the joint pdf corresponds to the Boltzmann distribution. If *I* also includes a crystallographic data set sufficient to define the native structure precisely, the joint pdf is a Dirac delta function centered on the native atomic coordinates. For simplicity, we omit *I* from notation in the rest of the paper.

We now wish to estimate the joint pdf for a given protein from a sample of the native structures for different proteins, deposited in the PDB. To minimize the needed size of the sample and to derive a joint pdf for any protein sequence, we seek to approximate the joint pdf *p* in terms of pdfs for all pairs of atoms in the system, (i.e., pair pdfs); a pair pdf will depend only on the type and position of the two atoms, not on the whole sequence.

As suggested above, the joint pdf *p* can be approximated by a normalized product of the pair pdfs for all protein atom pairs:

The denominator is derived from the condition that the joint pdf must be a product of single body pdfs when all the pair pdfs are uncorrelated with each other. The terms in the denominator, , are single-body distribution functions that depend only on the composition of the protein and the total volume of the system. In other words, is the number density of atom *i,* equal to the reciprocal volume of the system. Because is constant for a given protein, it does not impact on the rank order of different conformations and is ignored here.

In the context of the statistical mechanical liquid state theory, Equation 1 is also known as the Kirkwood superposition approximation (Kirkwood 1935). The superposition approximation would be exact only if all the pair pdfs were mutually independent from each other . The pair pdfs of atom pairs are generally interdependent because each atom in the system interacts with more than one other atom; for example, a major source of interdependence of pair pdfs for nonbonded atoms within the same amino acid residue are the chemical bonds. For simple dense liquids, the ratio between the exact three-body distribution and its two-body approximation ranges from 0.8 to 1.2 (Alder 1964; Rahman 1964). In general, the Kirkwood approximation of the joint pdf by pair pdfs is clearly more accurate than a product of *N* single-body pdfs, .

It is tempting to equate interdependence with redundancy and thus minimize the problem by including only a subset of atoms (e.g., only C_{β} atoms) in the joint pdf. However, it was found empirically that such simplifications reduce the accuracy of the resulting statistical potentials (Samudrala and Moult 1998; Lu and Skolnick 2001; Melo et al. 2002; Zhou and Zhou 2002). A probable reason is that the all atom pair pdfs jointly encode the preferred relative orientations between whole residues. Correspondingly, it appears to be possible to reduce the number of atoms considered in the joint pdf without sacrificing its accuracy by using orientation-dependent terms (Buchete et al. 2004b), albeit this reduction comes at a cost of introducing additional degrees of freedom into each term.

A general reduction of the joint pdf to lower-order pdfs is provided by the Bogolyubov–Born–Green–Kirkwood–Yvon hierarchy of a chain of integral equations connecting the *N*-body pdf with simpler pdfs (McQuarrie 1975). Therefore, in principle, the formalism developed here for deriving the joint pdf as a sum of pairwise terms can also be applied to derive the joint pdf approximated by a sum of higher-order terms.

The joint pdf may in principle be improved beyond the superposition approximation by iteratively modifying the individual terms so as to maximize the discrimination between the native and non-native structures (Thomas and Dill 1996a). Although this approach has been applied successfully to a contact statistical potential, it is less likely to work well for the larger parameter space of an atomic distance-dependent statistical potential, such as the one developed here.

### Calculation of the pair pdf from the distance pdf estimated from a single sample native structure

We now estimate the pair pdf for all atom pairs (*i,j*), using a single sample native structure. A structure is defined by internal coordinates that are invariant with respect to translation and rotation. Thus, the interparticle distance *r* between and is the most relevant internal coordinate for a pair of atoms. Consequently, the distribution that can be estimated directly from a sample native structure is the distance pdf for a pair of atom types:

where *m* and *n* denote the atom types and *N _{mn}*(

*r*) is the number of atom type pairs (

*m*,

*n*) at a distance within [

*r*,

*r*+ Δ

*r*]. The distance pdf is proportional to the number of (

*m*,

*n*) pairs in a spherical shell of volume 4

*πr*

^{2}Δ

*r*; thus, the density of the (

*m*,

*n*) pairs in the shell is

*p*(

_{mn}*r*)/4

*πr*

^{2}Δ

*r*. For a finite and nonspherical native structure, only a fraction ξ(

*r*) of the spherical shell between

*r*and

*r*+ Δ

*r*centered on is occupied by protein atoms (0≤ξ(

*r*)≤1) (▶). Thus, the density of the (

*m*,

*n*) pairs at the distance

*r*is

*p*(

_{mn}*r*)/[4

*πr*

^{2}ξ(

*r*)].

**Schematic representation of the reference state. (**

*A*) An illustration showing why only a fraction of a spherical shell generally contributes to the normalization function (Equation 3). (

*B*) A pair of noninteracting atoms in a protein is modeled

**...**

Next, we need to relate the distance pdf *p _{mn}*(

*r*) to the pair pdf . The probability of finding atom

*i*at and atom

*j*at is . Therefore, the pair pdf is the product of the pair probability and the (

*m*,

*n*) pair density:

where *n*(*r*) is the normalization function equal to 4*πr*^{2}ξ(*r*), and *m* and *n* are the types of atoms *i* and *j*, respectively. As mentioned above, the single-body pdf is the number density of atom *i* and is ignored because it does not impact on the ranking of different conformations of the same protein.

### Normalization function n(r; a) for a single sample native structure

The calculation of the normalization function *n*(*r*) is not straightforward because the native structures are finite and varying in size (▶). Therefore, we explicitly denote *n*(*r*) as dependent on the size *a* of the sample native structure, *n*(*r*;*a*). We define the size *a* to be the radius of the sphere of uniform density that has the same radius of gyration *R _{g}* as the sample native structure; thus, . Similarly, for clarity, we also denote the distance pdf

*p*(

_{m,n}*r*) as

*p*(

_{m,n}*r*;

*a*).

The key simplification in the calculation of the normalization function *p _{m,n}*(

*r*;

*a*) is as follows: We construct a special state (i.e., the reference state) for which the calculation of

*p*(

_{m,n}*r*;

*a*) is analytically tractable and then assume that this

*p*(

_{m,n}*r*;

*a*) is applicable to any protein of size

*a*. We define the reference state for a sample native structure with the radius of gyration

*R*to be a sphere with the same radius of gyration and density, but with uncorrelated uniformly distributed atomic positions (▶); this reference state is independent of the composition. The assumption of uncorrelated uniform atomic density is grounded in the maximum entropy principle corresponding to no prior knowledge about the native structures. It is difficult to justify this particular reference state, especially its finite spherical attribute, other than by intuition and the performance of the corresponding statistical potential in protein structure prediction (Results).

_{g}According to Equation 3, in a reference state with uncorrelated positions of atoms *i* and *j*
, the normalization function *n*(*r*;*a*) is equal to the distance pdf . Although and *n*(*r*;*a*) for a sphere have already been calculated (Deltheli 1919; Hammersley 1950; Lord 1954; de Smith 1977; Tu and Fischbach 2002; Garcia-Pelayo 2005), we re-derive them here for completeness.

We start by placing a stationary point (*sp*) on the center of the sphere encompassing the reference state (*h* = 0) while allowing a mobile point (*mp*) to move freely on the surface of a smaller “probe” sphere at a distance *r* from *sp* (small sphere in ▶). Because the mobile point cannot be outside of the reference sphere, the partial normalization function *m*(*r*;*a*) for an atom at the center of the reference sphere is

Next, we offset the stationary point from the center of the reference sphere by distance *h* ≤ *a*. For distance *r* smaller than *a* − *h*, the mobile point must reside inside the sphere; thus, *m*(*r*;*a*) remains 4π*r*^{2}. For *a* − *h* ≤ *r* ≤ *a* + *h*, the mobile point touches the reference sphere surface; thus, *m*(*r*;*a*) is proportional to the intersecting surface area of the probe sphere that remains within the reference sphere (Wodak and Janin 1980). Therefore, *m*(*r*;*a*) of the offset point is

The normalization function is thus determined by integrating *m*(*r*;*a*) over all possible offsets *h*:

which yields the normalization function:

where *r _{c}* is some upper bound on the range of the statistical potential. Equation 7 is validated numerically by the histogram of one million pairs of randomly generated distances inside a 22 Å sphere (the average size of a ∼150 residue protein domain) (▶). The most probable distance lies at , which is ∼5% greater than the sphere radius. When

*r*is infinitesimally small,

*n*(

*r*;

*a*) approaches

*r*

^{2}; as the distance

*r*increases,

*n*(

*r*;

*a*) can be expressed as

*r*, where

^{α}*α*depends on both the distance

*r*and sphere radius

*a*. The effective exponent

*α*can be derived by taking the logarithm and then the first derivative of both sides of the definition

*m*(

*r*;

*a*) =

*r*; thus,

^{α}*a*of 22 Å (Fig.

**...**

and finally combining this result with Equation 7 (▶):

*r*(Equation 8). The dashed, thin, and thick curves show the effective exponents α(

*r*) for sphere radii

*a*of 20, 22, and 24 Å, respectively. The

**...**

As expected, the short and long-range asymptotic behaviors of the effective exponent α are α → 2 as *r* → 0 and α → 0 as *r* → , respectively.

### Using a sample of many native structures of varying size

We now need to derive the joint pdf from a sample of many native structures of varying size, which is nontrivial because both the distance pdf *p _{m,n}*(

*r*;

*a*) and the normalization function

*n*(

*r*;

*a*) depend on size

*a*of a sample structure. We note in passing that if we had a sufficiently large sample of native structures, we could subdivide it into subsets of proteins of equal size and then derive the joint pdf separately for each subset without the complication of combining the statistics from structures of varying size.

The dependence of both *p _{m,n}*(

*r*;

*a*) and

*n*(

*r*;

*a*) on protein size

*a*might suggest that their ratio, pair pdf , also depends on

*a.*However, we suggest that the pair pdf may be approximately independent of the protein size. While we are not able to support this approximation based on statistics, we can ground it in physics if we assume that the pair pdf reflects only the potential of mean force between the corresponding atom types (Equation 12). The potential of mean force between two atoms in a protein, in turn, should depend only on their chemical properties and their distance, not on the protein size. Thus, the pair pdfs derived from subsets of protein structures of different sizes will not vary, except for statistical fluctuations due to small sample sizes, and can thus be averaged to obtain a more accurate estimate of the pair pdf.

### Calculating DOPE

Based on the arguments and equations above, the complete calculation of DOPE is as follows. First, for each sample native structure, the distance pdf *p _{m,n}*(

*r*;

*a*) is estimated by Equation 2; the details about the sample of the native structures, the sampling of the distances, atom types, and implementation in MODELLER-8 are described in Materials and Methods. The normalization function

*n*(

*r*;

*a*) is calculated from Equation 7 using .

Second, for each atom type pair (*m,n*) in the sample native structure, the pair pdf is calculated using Equation 2 and 3.

Third, the weight *w _{s}* of the sample native structure is calculated as the ratio between the number of all atom pairs in this structure and the number of atom pairs in all sample structures, irrespective of their types.

Fourth, the pair pdf for the sample of all native structures is calculated as a weighted sum of the pair pdfs corresponding to the individual sample structures:

where index *s* runs over all sample native structures. This averaging procedure is based on the presumed independence of the pair pdf from the protein size, as rationalized above.

### Requirements needed for a physical interpretation of the joint pdf as the free energy

There are two approximations needed to relate the joint pdf (Equations 1–3) derived from a sample of native structures and the free energy of a protein in solvent. However, we do not argue that these approximations are actually accurate or physically correct. The first approximation is that the pair pdfs estimated from a sample of known native structures obey the Boltzmann statistics of a canonical ensemble at some temperature *T* (Sippl 1990). While this approximation is partly validated by the observed Boltzmann statistics of structural features (e.g., atomic distances) in a set of known native structures (Finkelstein et al. 1995), serious concerns about its correct interpretation remain (Finkelstein et al. 1995; Thomas and Dill 1996b). The second approximation is the superposition approximation (above). Importantly, we note that the derivation of our statistical potential is entirely independent of the hypothetical relationships outlined in this section.

The joint pdf *p* defines the *N*-body correlation function *g* (Hill 1956):

The total free energy *G* of the system can then be expressed in terms of the correlation function *g*:

where *k _{B}* is the Boltzmann constant. Therefore, an approximate free energy of a system is (Equations 1, 3, 9, 10):

where is the radial distribution function equal to *p _{m,n}*(

*r*)/

*n*(

*r*), and ū

_{i,j}(

*r*) is the potential of mean force for a pair of atoms .

Because and thus ū_{i,j}(*r*) = 0 for the reference state as defined above, the potential of mean force derived from the observed distance pdf *p _{m,n}*(

*r*) is

where and are the numbers of atom type pairs (*m*,*n*) at a distance *r* within [*r*, *r* + Δ*r*] for the “interacting” real system and the “noninteracting” reference state, respectively. This interpretation of our reference state is identical to that of the “discharged” state used for free energy calculations in statistical mechanics (Onsager 1933; Hill 1956). Equation 13 establishes the relation between the statistical potential derived from a sample of known structure and the potential of mean force.

## Results

### Comparison of distance-dependent statistical potentials

We compare the distance dependence of DOPE, DFIRE, and RAPDF for four representative pairs of atom types (main chain–main chain, main chain–side chain, hydrophobic side chain–hydrophobic side chain, and polar side chain–hydrophobic side chain) (Equation 12) (▶). For all four pairs, DOPE has a steeper repulsion at short distances. The Ile C_{α}–Leu C_{δ} and Asp C_{β}–Leu C_{β} pairs (i.e., main chain–side chain and polar side chain–hydrophobic side chain; ▶,▶) are very similar for all three statistical potentials. The structured distance dependence of the Cys N–Trp O main chain–main chain pair is present in DOPE as it is in DFIRE and RAPDF (▶). The minor difference between DOPE and DFIRE lies at ∼2.75 Å, where a small peak in DFIRE is absent in DOPE. The difference between DOPE and DFIRE is more pronounced for the Ile C_{β}–Leu C_{β} hydrophobic side chain–hydrophobic side chain pair, where DOPE lies between DFIRE and RAPDF.

### Native state detection

We first assess DOPE in terms of its ability to identify the native states in five multiple target decoy sets (▶), including *4state_reduced*, *fisa*, *fisa_casp3*, *lmds*, and *lattice_ssfit* decoy sets from the Decoys ‘R’ Us Web site (http://dd.stanford.edu). This assessment is relative to five other previously published scoring functions, including DFIRE, Rosetta, ModPipe-Pair, Modpipe-Surf, and Modpipe-Comb (see Materials and Methods). DFIRE, in particular, is one of the best performing atomic distance-dependent statistical potentials (Zhou and Zhou 2002). DOPE correctly identifies 28 native structures for 32 targets in five multiple target decoy sets, while DFIRE, Rosetta, ModPipe-Pair, Modpipe-Surf, and Modpipe-Comb are successful for 27, 14, 19, 7, and 18 targets, respectively (▶). All scores miss the native state of 1fc2 in the *fisa* set (except for Modpipe-Surf) and 1b0n-B, 1bba, and 1fc2 in the *lmds* set.

We also tested all six scoring functions on the 20 targets in the *moulder* decoy set derived by iterative target-sequence alignment and comparative model building (Materials and Methods). DOPE, DFIRE, Rosetta, ModPipe-Pair, and Modpipe-Comb are all able to identify 19 out of the 20 native structures from the total of 301 conformations. The single failure for these five scores was the only NMR structure, 2pna. Modpipe-Surf failed to identify two native structures (2pna and 1mup).

For all six decoy sets, DOPE correctly identifies 47 native states for 52 targets (90%), while DFIRE, Rosetta, ModPipe-Pair, Modpipe-Surf, and Modpipe-Comb succeed in 46, 33, 38, 25, and 37 cases (88%, 63%, 73%, 48%, and 71%), respectively.

### Correlation between the score and model error

The percentage of detected native states provides a useful but incomplete indication of the accuracy of a scoring function. In particular, it does not describe the correlation between the score of a model and its structural similarity to the native state, suggested by the funnel-shaped free energy landscape of protein folding. To quantify these score–error correlations for the six scoring functions, we calculated the individual and average score–error correlation coefficients between the scores and the C_{α} RMS errors for the *4state_reduced* decoy set (▶). ModPipe-Pair yields the highest average score–error correlation coefficient (0.69) among the six tested scoring functions, with DOPE and Modpipe-Comb following closely second (0.67). Moreover, ModPipe-Pair and DOPE both have the highest score–error correlation in three out of seven individual targets in the set.

The score–error correlation coefficients were also calculated for the *moulder* decoy set (▶). The examples of high, medium, and low DOPE score–error correlation coefficients for the 20 targets in the *moulder* test set are 0.92 (1bbh), 0.84 (1eaf), and 0.67 (1cew), respectively (▶). The score–error correlation coefficients from the *moulder* decoy set are generally higher than those for the *4state_reduced* set. The average DOPE score–error correlation coefficient over 20 targets (0.87) is slightly higher than that of DFIRE and Rosetta (0.85), while the coarse-grained scores tend to have lower correlation coefficients; the ModPipe-Comb average correlation is 0.82, and the ModPipe-Pair average correlation is 0.73 (▶). Notably, the DOPE score– error correlation coefficients for nine out of the 20 targets are ≥0.9, indicating a better performance of DOPE compared to DFIRE (6) and Rosetta (4).

*moulder*decoy set. (

*A*) High correlation, correlation coefficient

*r*= 0.92 (1bbh). (

*B*) Medium correlation,

*r*= 0.84 (1eaf). (

*C*) Relatively low correlation,

**...**

The high score–error correlation of DOPE suggests a relatively useful description of the non-native portion of the free energy surface. As a result, we expect DOPE to be more suitable than the alternative scoring functions for refining non-native structures as well as for selecting the most accurate model among a set of decoys without the native structure.

### Selection of the most accurate non-native model

Identification of the non-native structure closest to the native structure among a set of decoys is generally significantly more difficult than identification of the native structure. Even the actual free energy function would generally not succeed if the best model were far enough from the native state. Yet, it is this more difficult task that needs to be performed in realistic model assessments where the native structure is not available. Therefore, to further test the practical utility of DOPE, we assess each of the 300 models of the 20 targets in the *moulder* decoy set by DOPE and the five other scoring functions. For the *moulder* decoy set, DOPE is the most accurate score according to three assessment measures (▶) as follows.

Using ΔRMSD as the accuracy criterion, DOPE is the best of all six tested scores with average and median ΔRMSDs of 0.58 Å and 0.30 Å, respectively. DOPE outperforms DFIRE, Rosetta, and ModPipe-Comb, whose average (median) ΔRMSDs are 0.69 Å (0.44 Å), 0.87 Å (0.43 Å), and 1.23 Å (0.76 Å), respectively. In four cases, DOPE selects a model with the lowest ΔRMSD, a better performance than DFIRE and Rosetta (three cases each). The two structures (1cau and 1cew) for which DOPE failed to select a model with ΔRMSD < 2.0 Å are both difficult cases in the sense that they failed at least half of the tested scoring functions.

DOPE also performs better than other scores according to the *n*% enrichment measures (▶). The DOPE average 20% enrichment for the 20 targets is 3.92, compared to 3.85, 3.70, and 3.78 for DFIRE, ModPipe-Comb, and Rosetta, respectively. Ten-percent enrichment results in a similar ranking of the scoring functions. The difference in enrichment ratios between DOPE and DFIRE is more pronounced at the 10% threshold (6.25 compared to 6.00) than at the 20% threshold (3.92 compared to 3.85). This difference is primarily due to the relatively higher accuracy of DOPE in the near-native region.

The relative accuracy of a score can also be illustrated by the number of the 10% most accurate models identified by the score; there are 600 such top 10% models in the *moulder* decoy set (10% × 20 targets × 300 models per target). DOPE identifies 375 of these models, which is 15, 26, and 28 more than identified by DFIRE, Rosetta, and ModPipe-Comb, respectively.

## Discussion

We derived an atomic distance-dependent statistical potential from known native protein structures (DOPE), based on probability theory and without recourse to statistical mechanics (see Theory). Moreover, we related DOPE to a potential of mean force, based on several customary assumptions. We benchmarked DOPE and five other previously published scoring functions by using five multiple target decoy sets from the Decoys ‘R’ Us Web site as well as a set of 300 comparative models of varying accuracy for each one of 20 different sequences of known structure (see Results). DOPE is the best performing function in the detection of the native state, the correlation between the score and C_{α} RMS error, and the identification of the most accurate non-native model. The improvement results primarily from a more rigorous treatment of the reference state in the derivation of DOPE. Next, we first compare the theory of DOPE with other existing methods for deriving statistical potentials; second, we discuss the importance of the size of the spherical reference state of DOPE; and finally, we describe four regimes where DOPE tends to be less accurate: incomplete models, small structures, low-accuracy models, and NMR structures. We conclude by listing several current applications of DOPE.

### Comparison of statistical potential reference states

All statistical potentials depend on the same protein structure database (i.e., PDB). Therefore, the differences between the distance pdfs *p _{m,n}*(

*r*) of various statistical potentials depend only on the specific choice of the sample structures and are not significant conceptually. In contrast, significantly different definitions of the distance pdf for the reference state (Equation 3), which is equal to the normalization function

*n*(

*r*) (Equation 3) or equivalently (Equations 2 and 3), have been used in the derivation of different statistical potentials. For example, RAPDF uses a conditional pdf to construct a distance pdf for the reference state (Samudrala and Moult 1998), and AKBP relies on a mole fraction-dependent reference state function (Lu and Skolnick 2001). We now compare the DOPE

*n*(

*r*) function to that of DFIRE, which is the most similar statistical potential to DOPE.

A physical picture of noninteracting atoms in a finite spherical volume has inspired the DFIRE reference state (Zhou and Zhou 2002; Zhang et al. 2004), just as it did for DOPE. The DFIRE normalization function is *n*(*r*) = *r ^{α}*, relying on a constant effective exponent parameter α that is used for all sample native structures irrespective of their size. The optimal value of α was found empirically to be 1.57 (Zhou and Zhou 2002) and subsequently refined to 1.61 (Zhou and Zhou 2002, 2003). The DFIRE reference state captures an important feature of particle density in a finite spherical volume; namely, it does not grow with

*r*

^{2}, but with

*r*, where α is smaller than 2.

^{α}DOPE goes a step further in the definition of the reference state and the corresponding normalization function. The DOPE reference state is a sphere whose size reflects that of the sample native structure, but with a uniform uncorrelated atom density; the reference state is independent of the composition of the protein. In contrast to DFIRE, the DOPE normalization function is derived analytically, without any adjustable parameters. It turns out that α is not a constant but, in fact, a function of both the distance between the interacting atoms *r* and the sample native structure size *a* (Equation 8). Thus, the DFIRE reference state can be considered to be an empirical approximation of the DOPE theory. For example, the average (over *r* from 0 to 15 Å) effective exponent α for a 22 Å reference sphere is 1.63, which is very close to the effective exponent α of DFIRE (1.61). The DOPE reference state results in a more accurate (see Results) and presumably more broadly applicable statistical potential; in principle, even though derived from sample native structures of different sizes, it is applicable to models of any size. Moreover, it affords a greater opportunity for generalization to other kinds of statistical potentials and other future developments.

### The size of the reference state

The reference state and the corresponding normalization function *n*(*r*) depend on the reference sphere radius *a* (see Theory). To further illustrate the impact of the reference sphere on the accuracy of the DOPE potential, we derived a version of DOPE in which the pair pdf in Equation 3 was calculated with the normalization function for the single sphere size *a*. This limited version of DOPE is termed DOPE-*a*. DOPE-*a* is highly inaccurate when derived with an incorrect reference sphere radius *a*. For example, DOPE-16 cannot identify the native structure of 1bbh (▶). In contrast, DOPE-24 does correctly identify the 1bbh native state (▶). The scoring function derived from a reference state that is too small results in an erroneous preference for loosely packed structures because the short-range interactions are deemed to be more repulsive by the corresponding DOPE*-a* than by DOPE.

*moulder*decoy set with (

*A*) DOPE based on an underestimated radius of the reference sphere

*a of*16 Å.

**...**

We also tested DOPE-24 on the five Decoys ‘R’ Us decoy sets to elucidate the importance of using the multiple reference states in the derivation of DOPE. In summary, DOPE-24 is less accurate than DOPE. DOPE-24 successfully ranks all 18 native structures in the *4state_reduced*, *fisa_casp3*, and *lattice_ssfit* as the best scored model. However, DOPE-24 performs worse than DOPE on the *fisa* and *lmds* decoy sets, where DOPE-24 misidentified nine native structures, five more than did DOPE. Overall, DOPE-24 successfully identified only 23 native states. This comparison emphasizes the importance of tabulating the distance pdfs for different pairs of atom types by using a reference state of the appropriate size; the “one-size-fits-all” reference state incorrectly scales the contributions from proteins of all but one size, leading to a less accurate statistical potential.

### Accuracy of DOPE as the function of completeness of assessed model

In general, the failures in picking the native structure may be caused by a number different factors, which will be discussed in the following four sections. The first of these factors is the incompleteness of the assessed model. For example, the native interface between two domains in a single protein may be needed for its stability. In such a case, it is conceivable that neither a physics-based energy function nor a statistical potential will score the native state of an isolated domain correctly. There is not much that can be done about this problem, other than striving to assess biologically stable units of structure. A possible example of such a failure is 1b0n-B, whose crystal structure indicates that the stable unit is a dimer, not a monomer.

### Accuracy of DOPE as the function of assessed model size

Yet another difficulty in model assessment is a small size of an assessed model; for example, 1b0n-B, 1bba, and 1fc2 have only 31, 36, and 43 residues, respectively. DOPE, like other statistical potentials, is less accurate for smaller proteins (▶). There are two potential sources of errors in assessing small proteins. First, small proteins are assessed by a smaller number of pairwise terms, thus resulting in a larger statistical error of the final score. The number of individual pairwise terms in the scoring function is proportional to the square of the protein sequence length; thus, the relative statistical fluctuation of the final score (Equation 12) is inversely proportional to the sequence length.

Second, the statistical mechanics of large proteins, which contribute most of the distances toward the construction of a statistical potential, may be different from that of small proteins, in addition to the differences accounted for by varying *a*. For example, the relatively more aspherical structure of small protein domains makes the spherical reference states less accurate. Also, a small protein domain usually lacks a well-packed hydrophobic core. To maintain the 1:1 hydrophobic-to-polar residue ratio found in these proteins, a substantial fraction of hydrophobic residues must be exposed (Shen et al. 2005). This irregularity is not captured well by a statistical potential and thus causes assessment errors. In an attempt to quantify this problem, we derived and tested a statistical potential by using only small protein structures (data not shown). This specialized statistical potential did not perform better than the statistical potential constructed from structures of all sizes (i.e., DOPE), presumably because of the first problem that apparently cancels the gains made by using the specialized sample consisting of only small native structures.

### Accuracy of DOPE as the function of model accuracy

The performance of DOPE in selecting the most accurate model tends to increase with the accuracy of the best model in the decoy set. The average C_{α} ΔRMSD, score–C_{α} RMS error correlation coefficient, and 10% enrichment for high-accuracy targets (best model C_{α} RMS error <3.0 Å) in the *moulder* decoy set are 0.41 Å, 0.90, and 6.62, respectively. All three measures are significantly better than the averages of 0.58 Å, 0.87, and 6.25 for all 20 targets in the decoy set. This trend is also observed for other scoring functions to a lesser extent; for example, the average correlation coefficient of the Rosetta score exhibits slight improvement from 0.846 to 0.854 when limited to high-accuracy targets.

The dependence of DOPE performance on model accuracy is illustrated further by the relation between the median C_{α} RMS error and the score–error correlation coefficient for the 20 targets in the *moulder* decoy set (▶). The DOPE score–error correlation begins to decrease when the median model C_{α} RMS error is greater than ∼10 Å. In contrast, the Rosetta score–error correlation coefficients remain relatively stable (although lower than those of DOPE for median model C_{α} RMS error <10 Å) in all model accuracy ranges. This difference between DOPE and Rosetta is presumably due to the different information used in the construction of the two scoring functions. By construction, DOPE is based entirely on the native structures and lacks the ability to discriminate models with large C_{α} RMS errors. In contrast, Rosetta contains several physics-based terms, including electrostatics, hydrogen bonds, and solvation, making it possible at least in principle to assess non-native models more accurately based on the laws of physics. In conclusion, a combination of physics-based energy terms and DOPE may be able to improve DOPE's correlation with model accuracy when the C_{α} RMS error is large.

*moulder*decoy set. (Filled circles) DOPE, correlation coefficient of −0.62; (open circles) Rosetta, correlation coefficient

**...**

A more thorough comparison of the scoring functions would include a local minimization of each model with respect to each scoring function before the calculation of the final assessment score. Such a relaxation would make the results less sensitive to relatively small steric clashes in the models, which are especially problematic for scoring functions with stiff steric repulsion terms, such as Rosetta and molecular mechanics force fields in general. It was not feasible here to perform such minimizations with all tested scoring functions.

### Assessment of NMR structures

Another difficulty is the assessment of structures determined by NMR spectroscopy. For example, neither DOPE nor DFIRE is able to identify the native structure of 2pna in the *moulder* decoy set. Initially, the 2pna native structure was arbitrarily chosen to correspond to the first of the 22 separately listed structures in the 2pna PDB file. To elaborate, we also assessed all 22 native structures in the PDB file; the corresponding DOPE scores ranged from −8997 to −9391. However, even the best scoring native structure does not score better than some of the decoys, although the rank does improves from 103 to 81 for the first and best scoring native structures, respectively. The apparent decrease of DOPE's ability to identify native NMR structures compared to X-ray structures is presumably a consequence of both the derivation of DOPE from X-ray structures and the inherent relative inaccuracy of the NMR structures compared to X-ray structures. It is conceivable that a DOPE-like score derived exclusively from the NMR structures will perform better than the current DOPE.

### Applications of DOPE

Protein structure scoring functions have many applications (see introductory section). To facilitate applications of DOPE in particular, we implemented it in MODELLER-8, using cubic splines to interpolate between sampled points for smooth function values and first derivatives (see Materials and Methods) (http://salilab.org/modeller) (Sali and Blundell 1993; Fiser et al. 2000). This implementation allows us to use DOPE for both assessment of given structures as well as their refinement with optimization methods that depend on first derivatives, such as conjugate gradients and molecular dynamics. It also allows us to benefit from DOPE combined together with other scoring functionals that have been already incorporated in MODELLER.

So far, DOPE has already been applied to ab initio protein structure prediction (Colubri et al. 2006), protein–protein docking (Shen et al. 2005), various problems in comparative modeling, including fold assignment, template selection, sequence–structure alignment (John and Sali 2003; Eramian et al. 2006; Pieper et al. 2006), loop modeling (M.-Y. Shen and A. Sali, unpubl.), side chain modeling (B. Webb and A. Sali, unpubl.), refinement of whole models (B. Webb and A. Sali, unpubl.), and model assessment (Eramian et al. 2006), the modeling of quaternary structure restrained by small angle scattering spectra (F. Foerster, D. Agard, and A. Sali, unpubl.), as well as fitting into cryo-electron microscopy mass density maps combined with comparative modeling (Topf and Sali 2005; Topf et al. 2006).

In the future, further improvements and generalizations of DOPE will be facilitated by its rigorous statistical formulation, with clear assumptions and approximations, free of adjustable parameters. Ongoing work includes a comparison between statistical and physics-based potentials, which may result in a combined function with better accuracy in non-native regions, adapting the potential for maximum accuracy with small proteins, generalization of statistical potentials to multibody forms with a rigorous reference state, and inclusion of information about sequences that do not fold into a given native structure as well as conformations that are not the native structure for a given sequence.

## Materials and methods

### Sample native structures

The sample of the native structures used for the calculation of DOPE contains 1472 representative single chains from the PDB, determined by crystallography at ≤1.8 Å resolution and with an R-factor ≤0.25. These representative structures share <30% sequence identity with each other. The list was constructed with the PISCES Web server (Wang and Dunbrack 2003). No effort was made to exclude chains with chain breaks, ligands, and quaternary interactions.

### Implementation of DOPE

We calculated DOPE for all pairs of non-hydrogen atoms in each of the 20 standard residue types, ignoring the N-terminal and C-terminal nitrogen and oxygen atoms, respectively. Thus, there are a total of 158 residue-dependent atom types. Nine of these atom types include differently labeled but chemically equivalent atoms (i.e., NH1 and NH2 in Arg, OD1 and OD2 in Asp, OE1 and OE2 in Glu, CD1 and CD2 in Leu, CD1 and CD2 in Phe, CE1 and CE2 in Phe, CD1 and CD2 in Tyr, CE1 and CE2 in Tyr, and CG1 and CG2 in Val). The possibility of equivalent atom pairs existing in different protonation states (e.g., OD1 and OD2 in Asp) was not addressed here. Such alternative assignments are difficult to resolve because of the absence of the experimentally determined positions of the hydrogen atoms in most of the sample structures, although an iterative scheme to address the problem has been described recently (Weichenberger and Sippl 2006).

DOPE was tabulated for distances from 0 to 15 Å (*r _{c}*), with an interval of 0.5 Å (Δ

*R*). These values were based on prior work (Melo et al. 2002; Zhou and Zhou 2002). The interval counts are converted into the DOPE scores, as described in the Theory section, except for counts of zero, which are assigned a DOPE score of 10, corresponding to the least favorable score.

DOPE was implemented in MODELLER-8 (http://salilab.org/modeller) (Sali and Blundell 1993) and the molecular dynamics package TINKER (Pappu et al. 1998) (http://dasher.wustl.edu). The MODELLER implementation relies on cubic splines (Press 1992) that allow us to smoothly interpolate between the sampled histogram points of DOPE as well as analytically calculate its continuous first derivatives. Thus, we can use DOPE, potentially combined with other scoring functions, for an optimization of a given model, in addition to its assessment.

### Tested scoring functions

We assessed DOPE against five other scoring functions: DFIRE (Zhou and Zhou 2002), Rosetta (Simons et al. 1997, 1999; Misura et al. 2006), as well as ModPipe-Surf, ModPipe-Pair, and ModPipe-Comb (Melo et al. 2002). This selection of scores includes both single-body and two-body scoring functions, as well as coarse-grained and all-atom scoring functions. The coarse-grained residue-based scores are ModPipe-Surf (single-body), ModPipe-Pair (two-body), and ModPipe-Comb (combined). The all-atom distance-dependent statistical potentials are DOPE and DFIRE. Rosetta is an all-atom scoring function that includes both physics-based models and statistical potentials, quantifying stereochemistry, nonbonded interactions, and solvation.

We calculated the Rosetta score by the Rosetta program, kindly provided by the authors, using standard argument values (i.e., -score). The DOPE and three ModPipe scores were calculated by MODELLER-8 (http://salilab.org/modeller). We calculated the DFIRE scores for the *moulder* decoy set by the DFIRE program, also kindly provided by the authors, while the assessments of DFIRE by the five Decoys ‘R’ Us decoy sets were taken from the original description of DFIRE (Zhou and Zhou 2002).

### Decoy sets of protein structures

Six multiple decoy sets, including the *4-state_reduced*, *fisa*, *fisa_casp3*, *lmds*, *lattice_ssfit*, and *moulder* decoy sets, were used to evaluate the performance of the DOPE statistical potential. The first five decoy sets are available through Decoys ‘R’ Us (http://dd.stanford.edu). The *4state-reduced* decoy set, containing from 632 to 689 models per target (seven targets in total), was generated using a four-state off-lattice model with a conformational relaxation method (Park and Levitt 1996). The *fisa* and *fisa_casp3* decoy sets with four and three targets (500–1400 models per target), respectively, were obtained using a combination of a Bayesian scoring function and a simulated annealing protocol (Simons et al. 1997, 1999). The *lmds* decoy set with 215–500 models for each one of 10 primarily short targets, was obtained by a local optimization method and a reduced ENCAD energy function (Keasar and Levitt 2003). The largest *lattice_ssfit* decoy set, containing 2000 decoys for each of eight targets, was generated using a tetrahedral lattice model with the all-atom ENCAD energy function (Xia et al. 2000).

The *moulder* decoy set is derived by iterative target-template alignment and comparative model building of 20 target sequences only remotely related to their template structures, relying on MODELLER-6 (John and Sali 2003); it contains 300 models for each target, based on a wide range of target-template alignment accuracy.

All the target native structures in all decoy sets were determined by X-ray crystallography, except for 1bba in *lmds* and 2pna in *moulder*, which were determined by NMR spectroscopy.

### Assessment of scoring function accuracy

Scoring functions were tested by five different criteria: First, the rank of the native structure in the list of decoys sorted by the tested score (NR). Second, the fraction of the targets for which the native structure was the best scoring structure in a decoy set. Third, the Pearson correlation coefficient *r* between the scoring function and the C_{α} RMS error for the target decoys (the score–error correlation); the C_{α} RMS error was calculated by MODELLER-8, upon least-squares rigid body superposition of a model and the native structure. Fourth, the difference in the C_{α} RMS error between the best scored model and the best model (ΔRMSD); ideally, C_{α} ΔRMSD should be 0 Å. Fifth, the relative occurrence of the most accurate (Cα RMS error) *n*% models among the *n*% best scoring models compared to that for the entire decoy set (*n*% enrichment). The best possible enrichment ratio (i.e., all *n*% most accurate models are recognized by the scoring function) is 1/*n*% [i.e., (*n*%/*n*%)/*n*%]. For example, the 10%-enrichment ratio for the best possible scoring function is 10 (i.e., 1/0.10). In contrast, a random scoring function has the probability of *n*% to correctly identify *n*% most accurate models, thus its enrichment ratio is *n*%/*n*% = 1.

## Acknowledgments

We thank Chao Tang, Martin Karplus, Karl Freed, and Ken Dill for commenting on the manuscript, as well as David Eramian, John Chodera, Marc Marti-Renom, and Bianxiao Cui for very helpful discussions. We also thank Ben Webb for helping implement DOPE in MODELLER-8, and David Eramian for testing it. We acknowledge NIH R01 GM54762 and The Sandler Family Supporting Foundation for funding, as well as IBM and Intel for computer hardware.

## Footnotes

Reprint requests to: Min-yi Shen or Andrej Sali, Department of Biopharmaceutical Sciences, Byers Hall at Mission Bay, Suite 503B, University of California at San Francisco, 1700 4th St., San Francisco, CA 94158, USA; e-mail: gro.balilas@yms or gro.balilas@ilas; fax: (415) 514-4231.

Article and publication are at http://www.proteinscience.org/cgi/doi/10.1110/ps.062416606.

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- ROTAS: a rotamer-dependent, atomic statistical potential for assessment and prediction of protein structures.[BMC Bioinformatics. 2014]
*Park J, Saitou K.**BMC Bioinformatics. 2014 Sep 18; 15:307. Epub 2014 Sep 18.* - Improved protein structure selection using decoy-dependent discriminatory functions.[BMC Struct Biol. 2004]
*Wang K, Fain B, Levitt M, Samudrala R.**BMC Struct Biol. 2004 Jun 18; 4:8. Epub 2004 Jun 18.* - Reduced C(beta) statistical potentials can outperform all-atom potentials in decoy identification.[Protein Sci. 2007]
*Fitzgerald JE, Jha AK, Colubri A, Sosnick TR, Freed KF.**Protein Sci. 2007 Oct; 16(10):2123-39.* - Protein decoy sets for evaluating energy functions.[J Biomol Struct Dyn. 2004]
*Gilis D.**J Biomol Struct Dyn. 2004 Jun; 21(6):725-36.* - Recommendations for evaluation of computational methods.[J Comput Aided Mol Des. 2008]
*Jain AN, Nicholls A.**J Comput Aided Mol Des. 2008 Mar-Apr; 22(3-4):133-9. Epub 2008 Mar 13.*

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- Statistical potential for assessment and prediction of protein structuresStatistical potential for assessment and prediction of protein structuresProtein Science : A Publication of the Protein Society. 2006 Nov; 15(11)2507

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