Issue 
A&A
Volume 602, June 2017



Article Number  A73  
Number of page(s)  8  
Section  Cosmology (including clusters of galaxies)  
DOI  https://doi.org/10.1051/00046361/201630289  
Published online  15 June 2017 
Is cosmic acceleration proven by local cosmological probes?
^{1} Université de Toulouse, UPSOMP, IRAP, 31400 Toulouse, France
email: isaac.tutusaus@irap.omp.eu
^{2} CNRS, IRAP, 14 avenue Edouard Belin, 31400 Toulouse, France
Received: 19 December 2016
Accepted: 6 April 2017
Context. The cosmological concordance model (ΛCDM) matches the cosmological observations exceedingly well. This model has become the standard cosmological model with the evidence for an accelerated expansion provided by the type Ia supernovae (SNIa) Hubble diagram. However, the robustness of this evidence has been addressed recently with somewhat diverging conclusions.
Aims. The purpose of this paper is to assess the robustness of the conclusion that the Universe is indeed accelerating if we rely only on lowredshift (z ≲ 2) observations, that is to say with SNIa, baryonic acoustic oscillations, measurements of the Hubble parameter at different redshifts, and measurements of the growth of matter perturbations.
Methods. We used the standard statistical procedure of minimizing the χ^{2} function for the different probes to quantify the goodness of fit of a model for both ΛCDM and a simple nonaccelerated lowredshift power law model. In this analysis, we do not assume that supernovae intrinsic luminosity is independent of the redshift, which has been a fundamental assumption in most previous studies that cannot be tested.
Results. We have found that, when SNIa intrinsic luminosity is not assumed to be redshift independent, a nonaccelerated lowredshift power law model is able to fit the lowredshift background data as well as, or even slightly better, than ΛCDM. When measurements of the growth of structures are added, a nonaccelerated lowredshift power law model still provides an excellent fit to the data for all the luminosity evolution models considered.
Conclusions. Without the standard assumption that supernovae intrinsic luminosity is independent of the redshift, lowredshift probes are consistent with a nonaccelerated universe.
Key words: cosmology: observations / cosmological parameters / supernovae: individual: SNIa luminosity evolution
© ESO, 2017
1. Introduction
The cosmological concordance model (ΛCDM) framework offers a simple description of the properties of the Universe reproducing noticeably well a wealth of high quality observations. However, we do not know the true nature of the dark components of the ΛCDM model, which form about 95% of the energy content of the Universe. The ΛCDM model has become the standard cosmological model with the evidence for an accelerated expansion provided by the type Ia supernovae (SNIa) Hubble diagram (Riess et al. 1998; Perlmutter et al. 1999). However, there has recently been an important discussion in the literature concerning the ability of SNIa data alone to prove the accelerated expansion of the Universe (Nielsen et al. 2016; Shariff et al. 2016; Rubin & Hayden 2016; Ringermacher & Mead 2016).
In this paper we examine whether the accelerated nature of the expansion can be firmly established based not only on SNIa data, but also on the other lowredshift cosmological probes: the baryon acoustic oscillations (BAO), the Hubble parameter as a function of the redshift (H(z)), and measurements of the growth of structures (fσ_{8}(z)). Moreover, we do not assume that the intrinsic luminosity of supernovae is independent of the redshift; therefore, we consider a nuisance parameter accounting for some luminosity evolution of SNIa with redshift, and we consider a large variety of luminosity evolution models to be as general as possible. We discard highredshift data, such as cosmic microwave background (CMB), because they are sensitive to the early Universe physics and because our goal is just to assess whether measurements of the local Universe are sufficient to prove the accelerated expansion of the Universe, which, at least in the standard cosmological model, appears at low redshift. In order to do this, we consider a simple nonaccelerated model based on a power law cosmology (Dolgov 1997; Dolgov et al. 2014; Kaplinghat et al. 1999, 2000; Shafer 2015; Rani et al. 2015; Tutusaus et al. 2016), but we focus here on a cosmological model that behaves like a power law cosmology only at low redshift, while the model behavior at high redshift is irrelevant for the cosmological probes considered in this work. We denote this model by NALPL (nonaccelerated local power law). The power law cosmology states that the scale factor, a(t), evolves proportionally to some power of time, a(t) ∝ t^{n}. Since we are interested in proving the acceleration of the Universe, we limit n ≤ 1 to deal with a nonaccelerating universe at late time.
In Sect. 2 we briefly describe the cosmological models under consideration. In Sect. 3 we present the statistical tool used to determine the goodness of fit of the models to the data. In Sect. 4 we present the lowredshift probes used in this study: SNIa, BAO, H(z) and fσ_{8}(z), as well as the different luminosity evolution models considered. We provide the results in Sect. 5 and we conclude in Sect. 6.
2. Models
In this section we present the two models used in this analysis: the ΛCDM model and the nonaccelerated lowredshift power law cosmology (NALPL).
2.1. Cosmological concordance model
The flat ΛCDM model is the current standard model in cosmology thanks to its ability to fit the main cosmological data, SNIa (Betoule et al. 2014), BAO (Anderson et al. 2014), and the CMB (Planck Collaboration XIII 2016). This model assumes a flat RobertsonWalker metric together with FriedmannLemaître dynamics leading to the comoving angular diameter distance, (1)and the FriedmannLemaître equation, (2)where H_{0} is the Hubble constant and Ω_{i} is the energy density parameter of the fluid i. We follow Planck Collaboration XIII (2016) in computing the radiation contribution as (3)where Ω_{γ} represents the photon contribution and is given by (4)We fix^{1} the effective number of neutrinolike relativistic degrees of freedom, N_{eff} = 3.04 (Planck Collaboration XIII 2016), H_{0} = 67.74 km s^{1} Mpc^{1} (Planck Collaboration XIII 2016), and the temperature of the CMB today, T_{CMB} = 2.725 (Fixsen 2009). For simplicity, we fix H_{0} only for the radiation contribution in the ΛCDM model. This parameter is left free in the rest of the work.
2.2. Nonaccelerated lowredshift power law model
The local power law cosmology is formulated in such a way that the scale factor is related to the proper time through a power law relation, (5)at late time. The FriedmannLemaître equation reads (6)so that the comoving angular diameter distance yields (7)We limit the cosmological parameter n to be smaller or equal to 1 to have a nonaccelerated universe.
3. Method
In this section we review the statistical tool used to determine the ability of a model to fit the cosmological data.
To quantify the goodness of a fit we minimize the χ^{2} function given by (8)where u stands for the model prediction, while u_{data} and C hold for the observables and their covariance matrix, respectively. In order to perform the minimization and find the errors on the parameters, we use the MIGRAD application from the iminuit Python package^{2}. This package is the Python implementation of the former MINUIT Fortran code (James & Roos 1975).
We also compute the probability that a higher value for the χ^{2} occurs for a fit with ν = N−k degrees of freedom, where N is the number of data points and k is the number of parameters of the model, (9)where Γ(t,x) is the upper incomplete gamma function and Γ(t) = Γ(t,0) the complete gamma function. We use this value as a goodness of fit statistic. A probability close to 1 indicates that it is likely to obtain higher χ^{2} values than the minimum found, pointing to a good fit by the model.
When combining probes, we minimize the sum of the individual χ^{2} functions, i.e., we assume that we are dealing with statistically independent probes. Equation (9) is only valid for N data points coming from N independent random variables with Gaussian distributions. In this work we use the correlations within probes; therefore, our data points no longer come from independent Gaussian random variables. However, it has been shown in Tutusaus et al. (2016), through Monte Carlo simulations, that the impact of the correlations we are dealing with is negligible in Eq. (9).
4. Data samples
In this section we present the lowredshift probes, SNIa, BAO, H(z), and fσ_{8}(z), and the specific data samples used in this work.
4.1. Type Ia supernovae
Type Ia supernovae are considered standardizable candles useful to measure cosmological distances and break some degeneracies present in other probes, providing us precise cosmological measurements. The standard observable used in SNIa measurements is the distance modulus, (10)where d_{L}(z) = (1 + z)r(z) is the luminosity distance.
The standardization of SNIa is based on empirical observation that they form a homogeneous class whose variability can be characterized by two parameters (Tripp 1998): the time stretching of the light curve (X_{1}) and the supernova color at maximum brightness (C). In this work we use the joint lightcurve analysis for SNIa from Betoule et al. (2014). Given the assumption of the authors that supernovae with identical color, shape, and galactic environment have on average the same intrinsic luminosity for all redshifts, the distance modulus can be expressed as (11)where corresponds to the observed peak magnitude in the Bband restframe and α and β are nuisance parameters related to the time stretching and the supernova color, respectively. The M_{B} nuisance parameter takes into account the supernova dependence on host galaxy properties and is given by (12)where and ΔM are two extra nuisance parameters.
Concerning the errors and correlations of the measurements, we use the covariance matrix provided in Betoule et al. (2014), where several statistical and systematic uncertainties have been considered, such as the error propagation of the lightcurve fit uncertainties, calibration, lightcurve model, bias correction, mass step, dust extinction, peculiar velocities, and contamination of nontype Ia supernovae. It is important to stress that this covariance matrix depends on the α and β nuisance parameters; therefore, when performing a minimization we recompute the covariance matrix at each step.
Since we do not assume that the intrinsic luminosity of SNIa is independent of the redshift, we consider an extra nuisance term, Δm_{evo}(z), accounting for a possible evolution of the supernovae luminosity with the redshift, (13)Different phenomenological models for Δm_{evo}(z) can be found in the literature (see for example Drell et al. 2000; Linder 2006; Nordin et al. 2008; Ferramacho et al. 2009; Linden et al. 2009). In the absence of any clear physics governing this evolution, one stays at a phenomenological level and considers a bunch of different models. We can embed all the models studied in this paper into four categories, which are summarized in Table 1. These categories all possess two parameters, ϵ and δ.
Model B is equivalent to model 2 in Linden et al. (2009), while model C is a generalization of model 1 in Linden et al. (2009). Model D is a generalization of Ferramacho et al. (2009). Models C and D were initially motivated from a parameterization of the intrinsic luminosity ℒ → ℒ(1 + z)^{− ϵ} (Drell et al. 2000), while models A and B are more general to study the contribution of powers in z to the results.
Different evolution models for SNIa considered in this paper. All models have two different parameters, ϵ and δ.
Let us observe that when δ → 0, Δm_{evo}(z) becomes strongly degenerate with . Therefore, to avoid these kinds of parameter degeneracies, we consider three submodels fixing δ = 0.3, 0.5, and 1. We denote these submodels A1, A2, A3, B1, B2, B3, and so on. A lower δ power contribution models a luminosity evolution dominant at low redshift, while a higher δ power contribution leads to a luminosity evolution dominating at high redshift.
When using SNIa data, the set of nuisance parameters considered is . We consider Ω_{m} and n as cosmological parameters for the ΛCDM and the NALPL model, respectively.
4.2. Baryonic acoustic oscillations
The baryonic acoustic oscillations are the regular and periodic fluctuations of visible matter density in largescale structure. They are characterized by the length of a standard ruler, generally denoted by r_{d}. In the ΛCDM model, the BAO come from sound waves propagating in the early Universe and r_{d} is equal to the comoving sound horizon at the redshift of the baryon drag epoch, (14)where z_{d} ≈ 1060 and c_{s}(z) is the sound velocity as a function of the redshift. Verde et al. (2017) have shown that models differing from ΛCDM may have a value for r_{d} that is not compatible with r_{s}(z_{d}). Moreover, the integral in Eq. (14) is divergent for n ≥ 2/3 power law cosmologies. According to this, and in order not to delve into early Universe physics, we consider r_{d} as a free parameter.
In this work we use isotropic and anisotropic measurements of the BAO. The distance scale used for isotropic measurements is given by (15)while for the radial and transverse measurements of the ani sotropic BAO the distance scales are r(z) and c/H(z), respectively.
We use the values provided by 6dFGS (Beutler et al. 2011), SDSS – MGS (Ross et al. 2015), BOSS – CMASS, and LOWZ samples DR11 (Anderson et al. 2014; Tojeiro et al. 2014) and BOSS – Lyα forest DR11 (Delubac et al. 2015; FontRibera et al. 2014). We consider a correlation coefficient of 0.52 for the CMASS measurements and of − 0.48 for the Lyα measurements, while we assume the rest of the measurements to be uncorrelated. In order to take into account the nonGaussianity of the BAO observable likelihoods far from the peak, we follow Bassett & Afshordi (2010) by replacing the usual for a Gaussianlikelihood observable by (16)where S/N is the detection significance, in units of σ, of the BAO feature. We follow Tutusaus et al. (2016) in considering a detection significance of 2.4σ for 6dFGS, 2σ for SDSSMGS, 4σ for BOSSLOWZ, 6σ for BOSSCMASS, and 4σ for BOSSLyα forest.
When using BAO data, we add the following parameters to our set: { r_{d} × H_{0}/c, Ω_{m},n }. The latter two only apply for the ΛCDM model and NALPL model, respectively. No nuisance parameters are added.
4.3. Hubble parameter H(z)
There are two main methods to measure the evolution of the Hubble parameter with respect to the redshift: the socalled differential age method (Jimenez & Loeb 2002) and a direct measure of H(z) using radial BAO information (Gaztañaga et al. 2009). A detailed discussion on the systematic uncertainties of these methods can be found in Zhang & Ma (2010). In this work we use the compilation of independent H(z) measurements from Simon et al. (2005), Stern et al. (2010), Moresco et al. (2012), Busca et al. (2013), Zhang et al. (2014), Blake et al. (2012), Chuang & Wang (2013) provided in Farooq & Ratra (2013). When using H(z) measurements, we add the H_{0} parameter to our set of cosmological parameters under consideration. No nuisance parameters are added.
4.4. Growth rate
The measurements of the growth rate of matter perturbations offer an additional constraint on cosmological models. Their value depends on the theory of gravity used and it is well known that identical background evolution can lead to differente growth rates (Piazza et al. 2014). Let us first define the linear growth factor of matter perturbations as the ratio between the linear density perturbation and the energy density, (17)We can then derive the standard second order differential equation for the linear growth factor (Peebles 1993) (18)where the dot stands for differentitation over the cosmic time. Neglecting second order corrections, this differential equation can be rewritten with derivatives over the scale factor (Dodelson 2003) (19)This expression is only valid if we assume that dark energy cannot be perturbated and does not interact with dark matter. Once we obtained D by solving numerically Eq. (19), we can compute the growth rate as (20)and the observable weighted growth rate, fσ_{8}, as (21)where K is a normalization factor accounting for the root mean square mass fluctuation amplitude on scales of 8 h^{1} Mpc at redshift z = 0, σ_{8}, and the normalization of the growth factor. We do not use the observed value for σ_{8} since it requires some assumptions about the early Universe physics. Instead, we let the lowredshift observations choose the preferred value for this normalization.
In this work we use the measurements of fσ_{8}(z) from Beutler et al. (2012), Samushia et al. (2012), Tojeiro et al. (2012), Blake et al. (2012), de la Torre et al. (2013) provided in Macaulay et al. (2013), together with their correlations. When using these measurements we add the K parameter and Ω_{m}, for the NALPL model, to our set of parameters under consideration.
Fig. 1 Results obtained from lowredshift background probes. Top panel: bestfit values for Ω_{m}, n, ϵ, r_{d} × H_{0}/c, and H_{0} parameters for all the cosmological and luminosity evolution models under consideration. The values for these parameters when no luminosity evolution is allowed are represented with bands as a reference. Bottom panel: goodness of fit statistics and difference of the χ^{2} values, , for the luminosity evolution models under study. The vertical solid line in the left plot illustrates the goodness of fit statistics for the standard ΛCDM imposing no luminosity evolution. The various gray bands in the right plot show the strength of Δχ^{2} given by the Jeffrey scale (see the text for details). 

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Fig. 2 Results obtained from lowredshift background probes combined with measurements of the growth of matter perturbations. Top panel: bestfit values for Ω_{m}, n, ϵ, r_{d} × H_{0}/c, and H_{0} parameters for all the cosmological and luminosity evolution models under consideration. The values for these parameters when no luminosity evolution is allowed are represented with bands as a reference. Bottom panel: goodness of fit and values for the luminosity evolution models under study (see Fig. 1). 

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Fig. 3 Model predictions vs. observations for the best luminosity evolution model, ΛCDM B2 and NALPL B2 (together with the standard ΛCDM prediction, for illustrative purposes) for all the cosmological probes considered. In each prediction, we used the bestfit values obtained from the global fit. Top left: residuals of SNIa data with respect to the corresponding model. Top right: residuals of BAO data with respect to the corresponding model. The isotropic measurements of the BAO are represented with a circle and their observable is D_{V}(z) /r_{d}, while the stars stand for the radial measurements with observable r(z) /r_{d} and the squares stand for the transverse measurements with observable c/ (H(z)r_{d}). Bottom left: measurements of H(z)/(1 + z) together with the model predictions. Bottom right: measurements of fσ_{8}(z) and the different model predictions. 

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5. Results
We present the results of this work in two different steps. In the first place we focus on lowredshift background probes, namely SNIa, BAO, and H(z), and in the second step we add the measurements of the growth of matter perturbations.
The results obtained from lowredshift background probes only are presented in Fig. 1. In the top panel we show the bestfit values obtained for the Ω_{m}, n, r_{d} × H_{0}/c and H_{0} cosmological parameters, as well as the ϵ nuisance parameter for the different cosmological and luminosity evolution models under study. The blue region of the left panel corresponds to the value, and the error, obtained for Ω_{m} in the standard ΛCDM case, i.e., with no luminosity evolution. We can observe that all the obtained values for Ω_{m} are completely compatible with the standard ΛCDM value.
In the second panel we plot the exponent n of NALPL for each model, together with a colored band corresponding to the allowed values when no evolution is imposed. We can observe that all the obtained values are compatible with a slightly lower value than in the no evolution case.
In the third panel we present the nuisance parameter associated with the luminosity evolution for all the models under consideration. As expected, all the ΛCDM models are perfectly compatible with 0. On the contrary, the NALPL models clearly need some positive luminosity evolution to fit the data.
Concerning the r_{d} × H_{0}/c cosmological parameter, we can observe that the ΛCDM values are compatible with the no evolution case, while the values obtained for the NALPL models are compatible with a lower value. This is also the case for the H_{0} parameter, as we can see in the last panel.
Focusing on the ability of these models to fit the data, all of them provide a very good fit to the data with a goodness of fit statistic value of P(χ^{2},ν) > 0.9, as we can see in the left plot of the bottom panel of Fig. 1. We present the difference of χ^{2} values given by in the right plot of Fig. 1 bottom panel. It is important to notice that, in this case, Δχ^{2} is equal to the difference of widely used standard model comparison criteria, such as the Akaike information criterion (Akaike 1973) or the Bayesian information criterion (Schwarz 1978), because both ΛCDM and NALPL have the same number of free parameters and we are using the same data for the fits. However, we are only interested in the ability of NALPL to fit the data, and we are not in search of performing a model comparison against ΛCDM. In the plot we also show the standard Jeffrey scale (Nesseris & GarcíaBellido 2013) to provide a qualitative idea of the strength of the Δχ^{2} variation. We consider 0 ≤ Δχ^{2}< 1.1 as a weak variation (thus compatible χ^{2} values), 1.1 ≤ Δχ^{2}< 3 as a definite variation, 3 ≤ Δχ^{2}< 5 as a strong variation, and 5 ≤ Δχ^{2} as a very strong variation.
From these results, we can observe that most NALPL models (A1, B1, B2, C1, C2, C3, D2, and D3) are not only able to fit the data with a very high goodness of fit statistic, but their χ^{2} value is also compatible with that obtained for ΛCDM.
In Fig. 2 we present the results obtained when adding the measurements of the growth of matter perturbations to the lowredshift background probes. In the top panel we show the bestfit values for the cosmological and nuisance parameters. The obtained values for the ΛCDM models are completely compatible with the no luminosity evolution case, as in the previous case (Fig. 1). The only difference here are slightly smaller error bars due to the introduction of more data points. Concerning the NALPL models, we have an extra cosmological parameter, Ω_{m}, which is very well constrained, but the other parameters remain qualitatively compatible with the results from Fig. 1: the cosmological parameters n, r_{d} × H_{0}/c and H_{0} are compatible with lower values than for the no luminosity evolution case, while ϵ is clearly not compatible with 0.
In the bottom panel of Fig. 2 we provide the results for the goodness of fit statistic and the variation of the χ^{2} values. In the first plot we can observe that all models provide a very good fit to the data (P(χ^{2},ν) > 0.93), while in the second panel we show that most NALPL models (A1, B1, B2, C1, C2, C3, D2, and D3) have a χ^{2} value compatible with (or slightly better than) those provided by ΛCDM. From a model criteria point of view it is clear that NALPL is slightly disfavored because of the introduction of the extra Ω_{m} parameter. However, the importance of the Occam factor depends on the model criteria used and, as discussed before, our goal is not to test the NALPL model against ΛCDM to adopt this model as an alternative, but just to show that it can fit the observational data extremely well.
In Fig. 3, just for completeness and illustrative purposes, we present the prediction for all probes using the best lowredshift power law model (B2), ΛCDM B2, and ΛCDM imposing no luminosity evolution. We used the global bestfit values for the cosmological and nuisance parameters. It is clear that all three models are able to reproduce the observations extremely well.
Taking all the lowredshift probes into account (SNIa, BAO, H(z), and fσ_{8}(z)), a NALPL model is perfectly compatible with the data for several luminosity evolution models. This points to the fact that lowredshift probes do not definitively prove the acceleration of the Universe and that we need more precise lowredshift measurements to claim this acceleration firmly.
6. Conclusions
In this work we have analyzed the ability of the lowredshift probes (SNIa, BAO, H(z), and fσ_{8}(z)) to prove the accelerated expansion of the Universe. More precisely, we considered a nonaccelerating lowredshift power law cosmology and checked its ability to fit these cosmological data. Using only the lowredshift background probes, and not imposing the SNIa intrinsic luminosity to be redshift independent (accounting for several luminosity evolution models), we find that a nonaccelerated lowredshift power law cosmology is able to fit very well all the observations, for all the luminosity evolution models considered. Moreover, most of the NALPL models provide a value for the χ^{2} perfectly compatible with that obtained for ΛCDM.
When we add the measurements of the growth of matter perturbations, a nonaccelerated lowredshift power law cosmology is able to fit all the data extremely well for all the luminosity evolution models considered. As in the previous case, most of the NALPL models provide χ^{2} values that are perfectly compatible (or even slightly better) than those coming from ΛCDM.
The main conclusion of this work is that if we do not impose the SNIa intrinsic luminosity to be independent of the redshift, the combination of lowredshift probes is not sufficient to firmly prove the accelerated expansion of the Universe.
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All Tables
Different evolution models for SNIa considered in this paper. All models have two different parameters, ϵ and δ.
All Figures
Fig. 1 Results obtained from lowredshift background probes. Top panel: bestfit values for Ω_{m}, n, ϵ, r_{d} × H_{0}/c, and H_{0} parameters for all the cosmological and luminosity evolution models under consideration. The values for these parameters when no luminosity evolution is allowed are represented with bands as a reference. Bottom panel: goodness of fit statistics and difference of the χ^{2} values, , for the luminosity evolution models under study. The vertical solid line in the left plot illustrates the goodness of fit statistics for the standard ΛCDM imposing no luminosity evolution. The various gray bands in the right plot show the strength of Δχ^{2} given by the Jeffrey scale (see the text for details). 

Open with DEXTER  
In the text 
Fig. 2 Results obtained from lowredshift background probes combined with measurements of the growth of matter perturbations. Top panel: bestfit values for Ω_{m}, n, ϵ, r_{d} × H_{0}/c, and H_{0} parameters for all the cosmological and luminosity evolution models under consideration. The values for these parameters when no luminosity evolution is allowed are represented with bands as a reference. Bottom panel: goodness of fit and values for the luminosity evolution models under study (see Fig. 1). 

Open with DEXTER  
In the text 
Fig. 3 Model predictions vs. observations for the best luminosity evolution model, ΛCDM B2 and NALPL B2 (together with the standard ΛCDM prediction, for illustrative purposes) for all the cosmological probes considered. In each prediction, we used the bestfit values obtained from the global fit. Top left: residuals of SNIa data with respect to the corresponding model. Top right: residuals of BAO data with respect to the corresponding model. The isotropic measurements of the BAO are represented with a circle and their observable is D_{V}(z) /r_{d}, while the stars stand for the radial measurements with observable r(z) /r_{d} and the squares stand for the transverse measurements with observable c/ (H(z)r_{d}). Bottom left: measurements of H(z)/(1 + z) together with the model predictions. Bottom right: measurements of fσ_{8}(z) and the different model predictions. 

Open with DEXTER  
In the text 
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