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**Atmospheric Measurement Techniques**
An interactive open-access journal of the European Geosciences Union

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AMT | Articles | Volume 12, issue 9

Atmos. Meas. Tech., 12, 5155–5160, 2019

https://doi.org/10.5194/amt-12-5155-2019

© Author(s) 2019. This work is distributed under

the Creative Commons Attribution 4.0 License.

https://doi.org/10.5194/amt-12-5155-2019

© Author(s) 2019. This work is distributed under

the Creative Commons Attribution 4.0 License.

Special issue: Towards Unified Error Reporting (TUNER)

**Research article**
26 Sep 2019

**Research article** | 26 Sep 2019

The application of mean averaging kernels to mean trace gas distributions

- Karlsruhe Institute of Technology, Institute of Meteorology and Climate Research, Karlsruhe, Germany

- Karlsruhe Institute of Technology, Institute of Meteorology and Climate Research, Karlsruhe, Germany

**Correspondence**: Thomas von Clarmann (thomas.clarmann@kit.edu)

**Correspondence**: Thomas von Clarmann (thomas.clarmann@kit.edu)

Abstract

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To avoid unnecessary data traffic it is sometimes desirable to apply mean averaging kernels to mean profiles of atmospheric state variables. Unfortunately, application of averaging kernels and averaging are not commutative in cases when averaging kernels and state variables are correlated. That is to say, the application of individual averaging kernels to individual profiles and subsequent averaging will, in general, lead to different results than averaging of the original profiles prior to the application of the mean averaging kernels, unless profiles and averaging kernels are fully independent. The resulting error, however, can be corrected by subtraction of the covariance between the averaging kernel and the vertical profile. Thus, it is recommended to calculate the covariance profile along with the mean profile and the mean averaging kernel.

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von Clarmann, T. and Glatthor, N.: The application of mean averaging kernels to mean trace gas distributions, Atmos. Meas. Tech., 12, 5155–5160, https://doi.org/10.5194/amt-12-5155-2019, 2019.

1 Introduction

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More often than not satellite data retrievals are constrained because the
unconstrained profile retrieval on a given altitude^{1} grid would lead to an
ill-posed inverse problem. The constrained retrieval is more robust, but the
price to pay typically is, among other effects, a certain loss in vertical
resolution. The effect of the constraint is characterized by the averaging
kernel matrix (Rodgers, 2000).

Many applications of remotely sensed data involve comparison with independent
model or independent measurement data. If these comparison data are better
resolved than the remotely sensed data, the averaging kernel of the latter
has to be applied to the former to make the comparison meaningful (Connor et al., 1994). Otherwise, differences caused by the different altitude
resolution would mask scientifically significant differences. Unfortunately,
for a vertical profile of *n* values of an atmospheric state variable, the
related averaging kernel matrix is of the size *n*×*n*; that is to say, the
data traffic is dominated by the averaging kernel data while the data product of
interest, namely the profile, could be communicated with much less effort.
Often the data users are not interested in the individual measurements but
prefer to work, e.g., with monthly zonal mean profiles
(e.g. Hegglin and Tegtmeier, 2011).
In this case, it would be convenient if the data user could simply apply monthly
zonal mean averaging kernels to their better resolved monthly zonal mean data to
make them comparable to the coarser resolved zonal monthly mean measurements.
Unfortunately averaging
and application of the averaging kernel are not commutative. As soon as the
data and the averaging kernels covary, the application of the mean averaging
kernel to mean profiles gives a different result than the application of
individual averaging kernels prior to averaging. We solve this problem by
providing statistically inferred covariance terms, which can be used to correct
the related error. In the next section we describe the theoretical framework
used. As a case study, covariances applicable to trace gas profiles
retrieved from MIPAS (Michelson Interferometer for Passive Atmospheric Sounding,
Fischer et al., 2008) measurements are inferred in Sect. 3.
The varying importance of the covariance effect is
illustrated in Sect. 4. Section 5 is an
interlude where we investigate pitfalls regarding the applicability of
averaging kernels to comparison data, before a critical discussion of the
applicability of our suggested approach concludes the paper
(Sect. 6).

2 The formal concept

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We borrow the formal concept of retrieval theory from Rodgers (2000). The intended application of our study is, at worst, moderately nonlinear retrievals. That is to say, linear theory is assumed to be adequate for the characterization of the retrieval in terms of error estimation, assessment of vertical resolution, and so forth. Thus, we ignore all complications that may arise from nonlinearity and thus do not discuss the retrievals in an iterative setting. Within the framework of moderately nonlinear problems, our results are still applicable to the results of iterative retrievals.

The vertical resolution of a profile of an atmospheric state variable, e.g.,
temperature or the volume mixing ratio of a trace gas, with *n* grid points, is
usually characterized by the averaging kernel matrix **A** of size
*n*×*n*. Its elements are the partial derivatives $\frac{\partial \widehat{{x}_{i}}}{\partial {x}_{j}}$ of the estimated state variables ${\widehat{x}}_{i}$ with
respect to the true state variable *x*_{j}. While the indices *i* and *j*
typically run over altitude levels of one vertical profile, the concept as such
has a much wider range of applicability, e.g., horizontal averaging kernels
(von Clarmann et al., 2009a) or characterization of cross-dependence of
multiple species. In this study, we restrict ourselves to averaging kernels
of vertical profiles of single species. For a constrained retrieval of the
type

$$\begin{array}{}\text{(1)}& \widehat{\mathit{x}}={\mathit{x}}_{\mathrm{a}}+{\left({\mathbf{K}}^{T}{\mathbf{S}}_{y}^{-\mathrm{1}}\mathbf{K}+\mathbf{R}\right)}^{-\mathrm{1}}{\mathbf{K}}^{T}{\mathbf{S}}_{y}^{-\mathrm{1}}\left(\mathit{y}-\mathit{F}\left({\mathit{x}}_{\mathrm{a}}\right)\right),\end{array}$$

or any equivalent formulation of it,
where the $\widehat{\mathit{x}}$ vector represents the estimated profile,
*x*_{a} is an a priori profile, **K** is the Jacobian matrix
$\frac{\partial {y}_{i}}{\partial {x}_{j}}$, ^{T} indicates a transposed matrix,
**S**_{y} is the measurement error covariance matrix,
**R** is a regularization matrix, ** F** is the radiative transfer
function, and

$$\begin{array}{}\text{(2)}& \mathbf{A}={\left({\mathbf{K}}^{T}{\mathbf{S}}_{y}^{-\mathrm{1}}\mathbf{K}+\mathbf{R}\right)}^{-\mathrm{1}}{\mathbf{K}}^{T}{\mathbf{S}}_{y}^{-\mathrm{1}}\mathbf{K}.\end{array}$$

The state dependence of the averaging kernel is largely due to the state
dependence of the Jacobian **K**.
With the averaging kernel matrix introduced above, and using the linearization

$$\begin{array}{}\text{(3)}& \mathit{y}-\mathbf{F}\left({\mathit{x}}_{\mathrm{a}}\right)\approx \mathbf{K}(\mathit{x}-{\mathit{x}}_{\mathrm{a}}),\end{array}$$

Eq. (1) can be rewritten as

$$\begin{array}{}\text{(4)}& \widehat{\mathit{x}}=(\mathbf{I}-\mathbf{A}){\mathit{x}}_{\mathrm{a}}+\mathbf{A}\mathit{x}.\end{array}$$

The most common application of the averaging kernel matrix is the degradation of highly resolved vertical profiles to make them comparable to poorer-resolved profiles by application of the averaging kernel matrix of the poorer-resolved profile to the high-resolved profile (Connor et al., 1994):

$$\begin{array}{}\text{(5)}& {\mathit{x}}_{\mathrm{degraded}}=(\mathbf{I}-\mathbf{A}){\mathit{x}}_{\mathrm{a}}+\mathbf{A}{\mathit{x}}_{\text{highlyresolved}},\end{array}$$

where **A** and *x*_{a} refer to the poorer-resolved profile.
It goes without saying that the high-resolved profile has to be resampled on the
grid on which the application of the averaging kernel is performed, and, if
applicable, transformed to the same units (volume mixing ratio, number density,
etc.).

Sometimes a priori profiles are used that are all zero, e.g., for most gas profiles retrieved from MIPAS (von Clarmann et al., 2009b). This is often appropriate if a smoothing regularization (Steck and von Clarmann, 2001, building on Tikhonov, 1963) is used instead of an inverse a priori covariance matrix as suggested by Rodgers (1976, 2000). For these applications, Eq. (5) reduces to

$$\begin{array}{}\text{(6)}& {\mathit{x}}_{\mathrm{degraded}}=\mathbf{A}{\mathit{x}}_{\text{highlyresolved}}.\end{array}$$

The same is true if for all retrievals the same altitude-constant prior is used in combination with an averaging kernel with unity row sums associated with purely smoothing constraints.

Using

$$\begin{array}{}\text{(7)}& \mathrm{cov}(\mathbf{a},\mathit{x})=\langle \mathbf{A}\mathit{x}\rangle -\langle \mathbf{A}\rangle \langle \mathit{x}\rangle ,\end{array}$$

calculation of, e.g., zonal averages over *L* profiles renders^{2}

$$\begin{array}{}\text{(8)}& \begin{array}{rl}\langle \widehat{\mathit{x}}\rangle & =\langle (\mathbf{I}-\mathbf{A}){\mathit{x}}_{\mathrm{a}}+\mathbf{A}\mathit{x}\rangle \\ & =\langle {\mathit{x}}_{\mathrm{a}}\rangle -\langle \mathbf{A}\rangle \langle {\mathit{x}}_{\mathrm{a}}\rangle -\\ & \mathrm{cov}(\mathbf{A},{\mathit{x}}_{\mathrm{a}})+\langle \mathbf{A}\rangle \langle \mathit{x}\rangle +\mathrm{cov}(\mathbf{A},\mathit{x}),\end{array}\end{array}$$

where

$$\begin{array}{}\text{(9)}& \mathrm{cov}(\mathbf{A},\mathit{x})={\displaystyle \frac{\mathrm{1}}{L}}\sum _{l=\mathrm{1}}^{L}({\mathbf{A}}_{l}-\langle \mathbf{A}\rangle )({\mathit{x}}_{l}-\langle \mathit{x}\rangle ).\end{array}$$

cov(**A**,*x*_{a}) can be treated in an analogue way.

Often these correlations are close to zero, e.g., in the case of almost linear radiative transfer. In this case, Eq. (8) reduces structurally to Eq. (4) and can be reinterpreted in the sense of Eq. (5), applied to mean averaging kernels and profiles, as

$$\begin{array}{}\text{(10)}& \langle {\mathit{x}}_{\mathrm{degraded}}\rangle =(\mathbf{I}-\langle \mathbf{A}\rangle )\langle {\mathit{x}}_{\mathrm{a}}\rangle +\langle \mathbf{A}\rangle \langle {\mathit{x}}_{\text{highlyresolved}}\rangle .\end{array}$$

For all other cases, i.e., when the covariance terms
cov(**A**,*x*_{a}) and cov(**A**,** x**)
are nonzero, the respective additive corrections are necessary.

For a retrieval with *x*_{a}=**0** (or *x*_{a} constant
with altitude and a purely smoothing constraint), Eq. (8) simplifies to

$$\begin{array}{}\text{(11)}& \begin{array}{rl}\langle \widehat{\mathit{x}}\rangle & =\langle \mathbf{A}\mathit{x}\rangle \\ & =\langle \mathbf{A}\rangle \langle \mathit{x}\rangle +\mathrm{cov}(\mathbf{A},\mathit{x}).\end{array}\end{array}$$

cov(**A**,** x**) can be approximated by $\mathrm{cov}(\mathbf{A},\widehat{\mathit{x}})$, which can easily be evaluated statistically
from the available results and distributed to the data user along with the mean
averaging kernel 〈

For a retrieval with constant climatological *x*_{a} for the entire
sample of profiles we get

$$\begin{array}{}\text{(12)}& \begin{array}{rl}\langle \widehat{\mathit{x}}\rangle & =\langle (\mathbf{I}-\mathbf{A}){\mathit{x}}_{\mathrm{a}}+\mathbf{A}\mathit{x}\rangle \\ & ={\mathit{x}}_{\mathrm{a}}-\langle \mathbf{A}\rangle {\mathit{x}}_{\mathrm{a}}+\\ & +\langle \mathbf{A}\rangle \langle \mathit{x}\rangle +\mathrm{cov}(\mathbf{A},\mathit{x}).\end{array}\end{array}$$

For a retrieval where an individual prior *x*_{a} is used for each profile
retrieval; i.e., a prior that represents the best available information on the
current state not in a climatological sense, but, e.g., from independent
measurements specific to each measurement of the ensemble, it may also be
adequate to assume

$$\begin{array}{}\text{(13)}& \mathrm{cov}(\mathbf{A},\mathit{x})\approx \mathrm{cov}(\mathbf{A},{\mathit{x}}_{\mathrm{a}}),\end{array}$$

i.e., that the prior information is a good representation of the true atmospheric state and variability. In this case the correction by the covariance terms becomes approximately obsolete because

$$\begin{array}{}\text{(14)}& \begin{array}{rl}\langle (\mathbf{I}-\mathbf{A})& {\mathit{x}}_{\mathrm{a}}+\mathbf{A}\mathit{x}\rangle =\\ & \langle {\mathit{x}}_{\mathrm{a}}\rangle -\langle \mathbf{A}\rangle \langle {\mathit{x}}_{\mathrm{a}}\rangle -\mathrm{cov}(\mathbf{A},{\mathit{x}}_{\mathrm{a}})\\ & +\langle \mathbf{A}\rangle \langle \mathit{x}\rangle +\mathrm{cov}(\mathbf{A},\mathit{x})\approx \\ & \langle {\mathit{x}}_{\mathrm{a}}\rangle -\langle \mathbf{A}\rangle \langle {\mathit{x}}_{\mathrm{a}}\rangle -\mathrm{cov}(\mathbf{A},{\mathit{x}}_{\mathrm{a}})+\\ & \langle \mathbf{A}\rangle \langle \mathit{x}\rangle +\mathrm{cov}(\mathbf{A},{\mathit{x}}_{\mathrm{a}})=\\ & \langle {\mathit{x}}_{\mathrm{a}}\rangle -\langle \mathbf{A}\rangle \langle {\mathit{x}}_{\mathrm{a}}\rangle +\langle \mathbf{A}\rangle \langle \mathit{x}\rangle .\end{array}\end{array}$$

For retrievals performed in the log space, all this becomes slightly more complicated (e.g., Stiller et al., 2012). Equation (5) then reads

$$\begin{array}{}\text{(15)}& {\mathit{x}}_{\mathrm{degraded}}=\mathrm{exp}\left(\left(\mathbf{I}-\mathbf{A}\right)\mathrm{ln}{\mathit{x}}_{\mathrm{a}}+\mathbf{A}\mathrm{ln}{\mathit{x}}_{\text{highlyresolved}}\right),\end{array}$$

where **A** is $\frac{\mathrm{ln}{\widehat{\mathit{x}}}_{i}}{\mathrm{ln}{\mathit{x}}_{j}}$. For
log retrievals there is no obvious way to correct for the averaging
artifacts as long as the averaging is performed linearly in the volume mixing ratio space.
Since averaging of logarithmic retrievals in the logarithmic domain has its
own problems (Funke and von Clarmann, 2012), we do not pursue this option any further.

The issues discussed in this section have to be considered if mean averaging kernels are to be applied to mean profiles in the spirit of Eq. (5), in order to make mean profiles of different sources comparable.

3 Covariances

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The covariances between the averaging kernel matrices and the state vectors are calculated as

$$\begin{array}{}\text{(16)}& \begin{array}{rl}\mathrm{cov}(\mathbf{A},\mathit{x})& =\\ & {\displaystyle \frac{\mathrm{1}}{L}}\left(\sum _{l=\mathrm{1}}^{L}({\mathbf{A}}_{l}-\langle \mathbf{A}\rangle )({\mathit{x}}_{l}-\langle \mathit{x}\rangle )\right)=\\ & {\displaystyle \frac{\mathrm{1}}{L}}\left(\sum _{l=\mathrm{1}}^{L}{\mathbf{A}}_{l}{\mathit{x}}_{l}-{\displaystyle \frac{\mathrm{1}}{L}}\sum _{l=\mathrm{1}}^{L}{\mathbf{A}}_{l}\sum _{l=\mathrm{1}}^{L}{\mathit{x}}_{l}\right),\end{array}\end{array}$$

where *L* denotes the sample size; we divide by *L* instead of *L*−1 because
the latter would entail an inconsistency with Eq. (8) and
Eqs. (11–14). The formulation in the lowermost line of
Eq. (16) is computationally more efficient. For our case
study, averaging kernel matrices and state vectors retrieved from limb emission
spectra measured by the MIPAS are used. The general processing
scheme is described by von Clarmann et al. (2003b, 2009b).
We study covariances for MIPAS O_{3} and hydrogen cyanide (HCN) profiles (Laeng et al., 2018 and Glatthor et al., 2015, respectively).

To illustrate the relevance of the correction terms, we also present the normalized covariance term $\stackrel{\mathrm{\u0303}}{r}$ for each profile element:

$$\begin{array}{}\text{(17)}& {\stackrel{\mathrm{\u0303}}{r}}_{n}=\mathrm{cov}(\mathbf{A},\mathit{x}{)}_{n}/(\langle \mathbf{A}\rangle \langle \mathit{x}\rangle {)}_{n},\end{array}$$

where index *n* runs over the profile elements. The $\stackrel{\mathrm{\u0303}}{\phantom{\rule{0.25em}{0ex}}}$ symbol is used to
avoid confusion with the product moment correlation coefficient established by
Pearson (1895), for which *r* is often used as a symbol and is widely
used for normalization of covariances but causes confusion when
applied to correlations of matrices with vectors. For simplicity, we still call
the normalized covariance “correlation”; however, we do this without claiming equivalence
with its scalar counterpart.

4 Results

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Case studies have been performed using ozone and HCN vertical profiles retrieved from MIPAS measurements of 9 February 2009. The test data set consists of 1385 geolocations. This day was characterized by a significantly disturbed Arctic vortex. Figure 1 shows the covariances between the profiles and the averaging kernel matrices of ozone globally (solid black line) and for various latitude bands of different sizes (dashed and dotted lines). In general the values are largest at the extreme ends of the profiles, where the effect of the constraint on the retrieved profile is typically largest.

These results suggest that for MIPAS ozone in the middle and upper stratosphere the effect studied here can be safely ignored. Problems are limited to the upper troposphere, lower stratosphere and the mesosphere. The relevance of this effect can be judged better on the basis of the correlation profiles (Fig. 2). From 20 to about 60 km the effect is negligibly small for all latitude bands investigated in this case study. Only at the uppermost and lowermost altitudes does the effect become relevant. The large effects at lower altitudes are simply caused by normalization of the original covariances by low ozone mixing ratios.

To study HCN is particularly interesting in the tropical upper troposphere and lower stratosphere. This is because HCN has tropospheric sources and its pathway into the stratosphere is a particular research issue. The covariance effects can exceed 10 % (dashed violet and yellow lines) and thus need to be considered when mean profiles are used for quantitative analysis and mean averaging kernels are applied.

These case studies are not meant to be representative for other gases or
other instruments. Instead, they are shown to give an idea of the order
of magnitude this kind of effect can reach. Unless
cov(**A**,** x**) can be shown to be small, we recommend using
this covariance term for an additive correction when mean averaging kernels
are applied to averaged comparison data.

5 An important side remark

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The issue of the limited applicability of averaging kernels to independent comparison data deserves awareness. When averaging kernels of a measurement are applied to better resolved comparison data, it is almost always tacitly assumed that the atmospheric state represented by the measurement is the same as that of the comparison data and thus that the averaging kernel of the measurement can be safely applied to the comparison data. However, since averaging kernels are in general state dependent, a caveat is in order.

Application of the formalism of Connor et al. (1994) (our Eq. 5)
has its own specific problems, which fully apply to our proposed scheme. The
application of the averaging kernel matrix of a poorly resolved profile
*x*_{coarse} to a better resolved profile *x*_{fine} is
only adequate if both data sets describe approximately the same atmospheric
state, i.e., if the one profile is in the linear domain of the other. That is
to say, if the same Jacobians apply to both profiles. Otherwise it would be
necessary to construct an averaging kernel using the Jacobian **K**
evaluated for the atmospheric state represented by the profile
*x*_{fine} but with the measurement covariance matrix
**S**_{y} and the regularization matrix **R** corresponding to
the retrieval producing *x*_{coarse}. Within linear theory, the
state dependence of the Jacobian **K**, and as a result the state dependence
of the averaging kernel matrix **A** is often ignored. To do so is
justifiable as long as the profiles to be intercompared are sufficiently
similar. In this case the comparison will show reasonable agreement.

If, in turn, the profiles are very different, two components contribute to the
disagreement seen after application of the Connor method: first, the genuine
difference of the profiles and, second, any artifact caused by the inadequate
averaging kernels. Thus, in the logic of a testing scheme, good apparent
agreement hints further at genuine good agreement because it is
extremely unlikely that genuine differences that could survive the application
of the Connor method with the correct averaging kernel are “convolved
away”,^{3}
with the averaging kernel evaluated for the wrong atmosphere.

6 Discussion and conclusion

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We have identified the following problem: that it is not generally allowable to apply mean averaging kernels to mean atmospheric profiles in situations where the averaging kernels and the profiles covary. The relevance of this effect, however, depends on the instrument, species, latitude band and the altitude under investigation. To solve this problem, we have proposed a statistical correction scheme that involves the covariance between the averaging kernel and the profile. With this correction in place, the scheme suggested by Connor et al. (1994) to make better resolved vertical profiles of atmospheric state variables comparable to coarser resolved ones can also be applied to averaged profiles.

For data producers who distribute, in addition to their original retrievals, zonal mean data or similar data products, we recommend the following: along with the generation of zonal mean data and averaging kernels, the correlation profiles should be calculated. Compared to averaging kernels and covariance matrices they need negligible storage and cause negligible data traffic. In cases when zonal mean data have already been generated but mean covariance matrices and covariance profiles are not available, the huge input/output load associated with reading all individual averaging kernels may be prohibitive. In these cases one might consider estimating the mean averaging kernel and the covariance profile on the basis of a limited random sample out of the measurements that went into the zonal mean.

Data availability

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Data availability.

MIPAS data used in this study are available online at https://doi.org/10.5445/IR/1000098437 (Glatthor and von Clarmann, 2019).

Author contributions

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Author contributions.

TvC identified the problem, suggested the research method, proposed the solution and wrote the paper. NG critically reviewed the methodology, implemented the suggested solution as a computer program, performed the calculations and visualized the results. Both authors discussed and evaluated the results and elaborated the recommendation.

Competing interests

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Competing interests.

Thomas von Clarmann is associate editor of AMT but has not been involved in the evaluation of this paper.

Special issue statement

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Special issue statement.

This article is part of the special issue “Towards Unified Error Reporting (TUNER)”. It is not associated with a conference.

Acknowledgements

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Acknowledgements.

Norbert Glatthor acknowledges support by BMBF project SEREMISA (50EE1547). SPARC provided funding for the meetings of the “Towards Unified Error Reporting (TUNER)” Activity, the framework within which this research took place. The International Space Science Institute (ISSI) provided support and facilities for two TUNER International Team meetings. The authors also acknowledge support by the Open Access Publishing Fund of Karlsruhe Institute of Technology.

Financial support

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Financial support.

The article processing charges for this open-access publication were covered by a Research Centre of the Helmholtz Association.

Review statement

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Review statement.

This paper was edited by Nathaniel Livesey and reviewed by two anonymous referees.

References

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Connor, B. J., Siskind, D. E., Tsou, J. J., Parrish, A., and Remsberg, E. E.: Ground-based microwave observations of ozone in the upper stratosphere and mesosphere, J. Geophys. Res., 99, 16757–16770, https://doi.org/10.1029/94JD01153, 1994. a, b, c, d

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von Clarmann, T., Glatthor, N., Grabowski, U., Höpfner, M., Kellmann, S., Kiefer, M., Linden, A., Mengistu Tsidu, G., Milz, M., Steck, T., Stiller, G. P., Wang, D. Y., Fischer, H., Funke, B., Gil-López, S., and López-Puertas, M.: Retrieval of temperature and tangent altitude pointing from limb emission spectra recorded from space by the Michelson Interferometer for Passive Atmospheric Sounding (MIPAS), J. Geophys. Res., 108, 4736, https://doi.org/10.1029/2003JD003602, 2003b. a

von Clarmann, T., De Clercq, C., Ridolfi, M., Höpfner, M., and Lambert, J.-C.: The horizontal resolution of MIPAS, Atmos. Meas. Tech., 2, 47–54, https://doi.org/10.5194/amt-2-47-2009, 2009a. a

von Clarmann, T., Höpfner, M., Kellmann, S., Linden, A., Chauhan, S., Funke, B., Grabowski, U., Glatthor, N., Kiefer, M., Schieferdecker, T., Stiller, G. P., and Versick, S.: Retrieval of temperature, H_{2}O, O_{3}, HNO_{3}, CH_{4}, N_{2}O, ClONO_{2} and ClO from MIPAS reduced resolution nominal mode limb emission measurements, Atmos. Meas. Tech., 2, 159–175, https://doi.org/10.5194/amt-2-159-2009, 2009b. a, b

We use the term altitude in a generic sense, not limited to geometric altitude but for any vertical coordinate. Alternative vertical coordinates can be, e.g., pressure or potential temperature.

Here a caveat is in order. The average of profiles which are “optimal” in the sense of maximum a posteriori information and where the a priori information is the same for all averaged profiles is not the optimal average. This is because the weight of the a priori information will be too large in the average. A more thorough discussion of this issue, however, is beyond the scope of this paper.

We put this term in quotes to highlight that this method is, mathematically speaking, not a convolution. It is not even a numerical approximation of a convolution.

Special issue

Short summary

To avoid unnecessary data traffic it is sometimes desirable to apply mean averaging kernels to mean profiles of atmospheric state variables. Unfortunately, the application of individual averaging kernels to individual profiles and subsequent averaging will, in general, lead to different results than averaging of the original profiles prior to the application of the mean averaging kernels. This effect is investigated and a correction scheme is proposed.

To avoid unnecessary data traffic it is sometimes desirable to apply mean averaging kernels to...

Atmospheric Measurement Techniques

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